auditor choice in politically connected firms
TRANSCRIPT
DOI: 10.1111/1475-679X.12032Journal of Accounting Research
Vol. 52 No. 1 March 2014Printed in U.S.A.
Auditor Choice in PoliticallyConnected Firms
O M R A N E G U E D H A M I ,∗, † J E F F R E Y A . P I T T M A N ,‡A N D W A L I D S A F F A R§
Received 26 April 2011; accepted 15 September 2013
ABSTRACT
We extend recent research on the links between political connections andfinancial reporting by examining the role of auditor choice. Our evidencethat public firms with political connections are more likely to appoint a Big4 auditor supports the intuition that insiders in these firms are eager to im-prove accounting transparency to convince outside investors that they refrainfrom exploiting their connections to divert corporate resources. In evidenceconsistent with another prediction, we find that this link is stronger for con-nected firms with ownership structures conducive to insiders seizing privatebenefits at the expense of minority investors. We also find that the relationbetween political connections and auditor choice is stronger for firms operat-ing in countries with relatively poor institutional infrastructure, implying that
∗Moore School of Business, University of South Carolina; †SKKU Business School,Sungkyunkwan University (Seoul, Republic of Korea); ‡Memorial University of Newfound-land; §School of Accounting and Finance, The Hong Kong Polytechnic University.
Accepted by Philip Berger. We thank Najah Attig, Narjess Boubakri, Jean-Claude Cosset,Sadok El Ghoul, Mara Faccio, Clive Lennox, Pete Lisowsky, Stefan Sundgren, and especiallyan anonymous referee for their insights on an earlier version of this paper. Our paper has alsobenefited from comments from participants at the 2012 European Accounting AssociationConference, the 2011 Global Finance Conference, and seminars at various universities. Weappreciate financial support from Canada’s Social Sciences and Humanities Research Councilas well as excellent research assistance from Nabhomani Aggarwal, David Godsell, and ZeinaMehdi. Omrane Guedhami and Jeffrey Pittman gratefully acknowledge funding from the Cen-ter for International Business Education and Research at the University of South Carolina andthe CMA Professorship/Chair in Corporate Governance and Transparency at Memorial Uni-versity, respectively.
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Copyright C©, University of Chicago on behalf of the Accounting Research Center, 2013
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tough external monitoring by Big 4 auditors becomes more valuable for pre-venting diversion in these situations. Finally, we report that connected firmswith Big 4 auditors exhibit less earnings management and enjoy greater trans-parency, higher valuations, and cheaper equity financing.
1. Introduction
In response to calls for research on this issue (e.g., Wang, Wong, and Xia[2008]), we estimate the importance of corporate insiders’ political con-nections to auditor choice.1 Our analysis contributes to extant researchby isolating whether political connections affect the likelihood that publicfirms rely on Big 4 auditors that tightly constrain insiders’ discretion overfinancial reporting.2 Moreover, we examine three other research questions:(1) Are connected firms with ownership structures that leave minority in-vestors more vulnerable to expropriation by insiders more likely to appointBig 4 auditors?, (2) Are connected firms in countries with relatively weakgovernance institutions more eager to engage a Big 4 auditor?, and (3) Doconnected firms benefit from hiring a Big 4 auditor?
Political connections heighten the tension that insiders in public firmsexperience in their financial reporting incentives. These insiders could ex-ploit their position to deny outside investors by siphoning corporate re-sources that they later conceal by distorting the financial statements (e.g.,Shleifer and Vishny [1994], La Porta et al. [1998]). In other words, theymay manipulate accounting numbers to suppress information on actualeconomic performance in order to ensure that their diversionary practices,largely stemming from political cronyism and corruption, are kept hidden.In fact, Chaney, Faccio, and Parsley [2011] find that earnings quality islower in politically connected firms. Rendering the financial statements lessinformative to provide cover for expropriation activities would be evidentin the absence of a Big 4 auditor.
However, there are countervailing incentives pushing politically con-nected firms to improve disclosure. In particular, connected insiders whorefrain from self-dealing would prefer higher-quality financial reportingto ensure that outside investors realize this. It follows that such politicallyconnected firms would be more likely to appoint Big 4 auditors since in-vestors value accounting transparency for protecting their interests (e.g.,Watts and Zimmerman [1983], Dyck and Zingales [2004]). This argumentreflects that more reliable financial reporting helps prevent expropriationby dominant insiders and their political patrons.
1 Reinforcing the significance of our research, politically connected firms account for al-most 8% of the world’s stock market capitalization (Faccio [2006]).
2 Although Arthur Andersen dissolved during our study period, we follow convention bylabeling the large brandname public accounting firms and their predecessors as the Big 4.Choi and Wong [2007] review worldwide evidence implying that the Big 4 supply higher-quality audits, reinforcing the U.S. evidence that Francis [2004] comprehensively surveys.
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We evaluate which of these financial reporting incentives dominates byexamining whether auditor choice varies systematically with political ties.Given that recent evidence implies that connected firms suffer uniqueagency problems that may magnify the demand for external monitoring—for example, Qian, Hongbo Pan, and Yeung [2011] find that insiders’ ex-propriation of minority investors in China is more severe in politically con-nected firms—we extend research on political connectivity and financialreporting outcomes to include the role of auditor choice.
Our analysis leads to four primary insights. First, we provide evidence thatthe demand for Big 4 auditors is greater for politically connected publicfirms relative to their nonconnected counterparts matched, using alterna-tive techniques, on country, industry, size, ownership structure, and othercharacteristics. In various specifications, our coefficient estimates translateinto political affiliations materially increasing the likelihood that firms willappoint a Big 4 auditor by a range of 5–8%, with all other variables assignedtheir mean values.3 Second, we report that connected firms with ownershipstructures that intensify insiders’ incentives to divert corporate resourcesare even more likely to appoint Big 4 auditors. Third, we find that the linkbetween auditor choice and political ties is stronger in firms operating incountries with relatively poor governance institutions, implying that Big 4audits become more valuable for disciplining connected insiders in thesecountries. Finally, our results suggest that connected firms with Big 4 au-ditors exhibit lower earnings management and enjoy greater transparency,higher valuations, and cheaper equity financing.
Although our core results are robust to confronting this issue variousways (e.g., alternative matching procedures, controlling for firm hetero-geneity as well as an extensive set of country-level variables, and restrictingthe sample to firms with long auditor tenure), the potential endogeneitybetween auditor choice and political connections means that we cannotinfer causality from this analysis. We address another important issue by iso-lating the incremental role that connections play in auditor choice beyondownership characteristics, including large ultimate shareholding (e.g., Fanand Wong [2005]). In developing our predictions, we rely on prior re-search to motivate that political connections exacerbate agency conflictsbetween dominant large shareholders and outside investors (e.g., Morck,Stangeland, and Yeung [2000], Faccio [2006], Berkman, Cole, and Fu[2010], Qian, Hongbo Pan, and Yeung [2011]). Empirically, we employseveral strategies to better identify the link between connections and au-ditor choice. First, we separately control in all regressions for the equitystakes held by the ultimate shareholder and the state, which have beenshown to influence auditor choice (e.g., Fan and Wong [2005], Guedhami
3 To provide some perspective on the economic magnitude of our evidence, Fan and Wong[2005] estimate that raising the fraction of voting (cash flow) rights belonging to the ultimateowner one standard deviation from its mean value leads to hiring a Big 4 auditor becoming5% (2%) more likely.
110 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
Pittman, and Saffar [2009]). Second, we apply several matching techniquesto assemble a benchmark group of nonconnected firms against which weevaluate auditor choice in politically connected firms. Third, we conductcross-sectional analysis to examine whether the link between political con-nections and auditor choice varies with corporate ownership characteris-tics. In all of these estimations, we find that connections affect auditorchoice beyond the ownership effects.
The rest of this paper is organized as follows. Section 2 reviews priorresearch to develop the testable hypotheses. Section 3 outlines our data andreports descriptive statistics on the regression variables. Section 4 covers theempirical evidence and section 5 concludes.
2. Motivation
2.1 THE IMPACT OF POLITICAL CONNECTIONS ON AUDITOR CHOICE
Political connections can benefit firms in many ways.4 However, anotherperspective holds that they can also lead to value-destroying tunneling bydominant insiders eager to at least recover the costs incurred in develop-ing these ties (e.g., Morck, Stangeland, and Yeung [2000]). In fact, Qian,Hongbo Pan, and Yeung [2011] report that the share of earnings that in-siders expropriate from outside investors in China exceeds the collectivevalue that political connections generate for the firm. Controlling share-holders in connected firms may have more opportunity to divert corpo-rate resources since they tend to be subject to fewer disciplinary constraintsfrom regulators. For example, Berkman, Cole, and Fu [2010] find evidencefrom stock market returns in China implying that minority investors per-ceive that regulators will fail to protect their interests by strictly enforc-ing new governance standards when the firm has a controlling owner withpolitical connections.5 Similarly, recent U.S. research suggests that politi-cally connected firms that fraudulently exaggerate their earnings experi-ence more lenient monitoring from regulators relative to fraudulent firmswithout political connections (e.g., Correia [2010], Yu and Yu [2011]).
Our research is grounded in prior research implying that Big 4 audi-tors supply better monitoring than non–Big 4 auditors. However, a natural
4 These political benefits include preferential treatment in the form of access to credit fromstate-owned banks (e.g., Dinc [2005]); the receipt of government contracts (e.g., Agrawal andKnoeber [2001]); corporate bailouts in the event of financial distress (e.g., Faccio, Masulis,and McConnell [2006]); lower tax burdens (e.g., Adhikari, Derashid, and Zhang [2006]);lax regulatory enforcement (e.g., Berkman, Cole, and Fu [2010]); and greater allocation ofgovernment investment during financial crises (e.g., Duchin and Sosyura [2012]).
5 However, evidence from a single country may not generalize elsewhere. For example, al-though there is extensive research on political connections in Indonesia, Faccio, Lang, andYoung [2001] caution against extrapolating inferences from there given its weak capital mar-ket institutions and poor corporate transparency. Rather than the unique conditions in playwhen focusing on a single country, we analyze the importance of connections worldwide toauditor choice to justify more general insights.
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question is whether the Big 4 outperform other auditors outside the UnitedStates where legal institutions governing investor protection are more be-nign. Some equity pricing evidence suggests that the severe exposure tocivil lawsuits confronting auditors in the United States is responsible fora major fault line that separates this country from the rest of the worldon differential audit quality (e.g., Khurana and Raman [2004], El Ghoul,Guedhami, and Pittman [2012]). Although both reputation incentives andlitigation shape Big 4 audit quality in the United States (e.g., Baber, Kumar,and Verghese [1995], Mansi, Maxwell, and Miller [2004]), the Big 4’s inter-est in protecting their reputations is largely behind their audits becomingeconomically distinct in other countries where it is harder for investors torecover damages when audit failure occurs.
In short, prior research suggests that reputation incentives are sufficientto generate an audit quality differential in countries with mild private en-forcement against auditors. Consistent with theory (e.g., DeAngelo [1981],Rogerson [1983]), this evidence implies that large auditors with valuablereputations at stake provide stricter monitoring. For example, recent re-search on German (Weber, Willenborg, and Zhang [2008]) and Japanese(e.g., Skinner and Srinivasan [2012]) firms supports the reputation expla-nation for audit quality in countries that impose minimal discipline onauditors in the form of holding them liable for violating securities laws.6
Moreover, Big 4 auditors with global practices may provide uniformly high-quality assurance services worldwide to avoid undermining their reputa-tions (e.g., Humphrey, Loft, and Woods [2009]). Altogether, this researchhelps justify our focus on the importance of Big 4 auditors to constrain-ing insiders in politically connected firms against distorting their financialstatements.
Politically connected firms may be reluctant to appoint Big 4 auditorsto improve accounting transparency since prior research suggests thatthey have access to cheap loans from state-owned banks anyway (e.g.,Dinc [2005], Claessens, Feijen, and Laeven [2008]). Moreover, Leuz andOberholzer-Gee [2006] find that Indonesian firms with close connectionsto the state avoid raising capital from arm’s length sources that insist onmore transparency since they are eager to conceal transactions benefit-ing controlling insiders and their political backers. In motivating their re-search on the impact of politically charged events on the release of negativefinancial news by Chinese state-owned enterprises, Piotroski, Wong, andZhang [2008, p. 3] explain that: “transparency will limit the ability of politi-cians and managers to consume their private benefits of control by expos-ing poor governance . . . ” They find that connected firms heavily suppress
6 Additionally, Fan and Wong (2005) find that Big 4 auditors improve corporate gover-nance in East Asia, a region where there is hardly any implicit insurance coverage availableto investors in the event of audit failure. In another study on this low-litigation region, Mit-ton [2002] finds evidence corroborating that investors perceive that Big 4 auditors improveaccounting transparency in East Asian firms.
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information, which Piotroski, Wong, and Zhang [2008] partly attribute tothese firms’ incentives to hide from minority shareholders’ expropriation-related activities stemming from political cronyism and corruption.
Similarly, Stulz [2005] concludes that the threat of public exposure has asobering impact on whether politicians and insiders collude to extract pri-vate benefits. In evidence implying that smaller investors are marginalizedin these situations, Fan, Wong, and Zhang [2007] find that Chinese firmswith politically connected CEOs seldom appoint directors representing mi-nority shareholders, which stands in sharp contrast to the large fractionof their directors who are affiliated with the largest shareholder or gov-ernments. Faccio [2006] reports some cross-country evidence from stockprice reactions to announcements that politicians were joining the boardsof firms in which outside investors perceived that controlling sharehold-ers and their political allies would exploit these connections to expropriatethem. Her evidence reconciles with prior research implying that politiciansextract rents from the firms that they manage (e.g., Shleifer and Vishny[1994]). Politically connected firms in Canada tend to have concentratedownership (e.g., Morck, Stangeland, and Yeung [2000]), reinforcing thatoutside investors have valid concerns that insiders in these firms may con-sume private benefits to their detriment. Accordingly, although prior re-search supports that political connections can add value to all sharehold-ers, they can also engender agency conflicts between dominant insiders andoutside investors.
Given their diverging accounting transparency incentives, it remains un-clear whether insiders in politically connected firms turn to Big 4 auditorsto lower information asymmetry. In one direction, the stricter monitoringimposed by a higher-quality auditor would reduce insiders’ discretion todistort financial reporting. Consequently, financing costs (valuations) forconnected firms with Big 4 auditors will fall (rise) under this argumentsince accounting transparency helps outside investors identify any expro-priation. In the other direction, connected insiders extracting private ben-efits may choose a non–Big 4 auditor to hide that they are depriving out-side investors. Accompanying political ties according to this argument arestrong incentives for insiders to deliberately render the financial statementsless informative by hiring a lower-quality auditor to help cover their tracks.
This underlying tension in insiders’ financial reporting incentives moti-vates our analysis (Fan and Wong [2005]). We focus on how firms with polit-ical connections weigh the marginal benefits of appointing a Big 4 auditor(e.g., cheaper equity pricing and higher firm value) against its marginalcosts (e.g., narrower scope to expropriate). Big 4 audits are a two-edgedsword from the standpoint of insiders: negative when they are extractingprivate benefits and positive when they internalize outside investors’ bestinterests. The importance of political connections to the demand for Big 4audits remains an empirical question that hinges on which financial report-ing incentive dominates. We, largely for expositional convenience, predictthat firms with political ties tend to hire higher-quality auditors to credibly
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commit to refrain from diverting corporate resources (all hypotheses arestated in the alternative):
H1: In comparison to other public firms, politically connected firms aremore likely to appoint Big 4 auditors.
2.2 THE MEDIATING ROLE OF FIRMS’ OWNERSHIP STRUCTURES
Ownership characteristics may shape the role that political connectionsplay in auditor choice. La Porta et al. [2002] report that ownership struc-tures in which dominant shareholders exercise control despite owning onlya small fraction of the firm’s cash flow are widespread around the world.7
Mapping into our research questions, Fan and Wong [2005] find that thedemand for external monitoring by a high-quality auditor in East Asianfirms rises when the controlling shareholder’s voting rights exceed her cashflow rights. Given that minority investors become more susceptible to ex-propriation as the ownership-control gap widens (e.g., Shleifer and Vishny[1997], Joh [2003], Faccio [2006]), we expect to observe that such con-nected firms are even more likely to appoint Big 4 auditors to reduce infor-mation asymmetry.
Similarly, firms with a single large shareholder suffer worse agency con-flicts with outside investors. Pagano and Roell [1998] model that firms withmultiple large shareholders—with both the ability (via their voting rights)and the incentive (via their cash flow rights) to actively cross-monitor eachother—prevent insiders from accruing private benefits. In contrast, ratherthan requiring the consent of a coalition of large shareholders, a singledominant shareholder can unilaterally dictate corporate policy, includingdiversionary activities (Bennedsen and Wolfenzon [2000]). It follows thatstrict external monitoring by Big 4 auditors is more valuable to outside in-vestors in connected firms when they cannot rely on committed internalmonitoring by multiple major shareholders to protect their interests.
Finally, large shareholders in business groups can exploit, for example,pyramidal ownership to secure control rights that far exceed their equity
7 The collapse of Parmalat, the Italian dairy-and-food conglomerate, in 2003 illustrates theinterplay between ownership structure, political connections, and insiders disguising their di-version of corporate resources by manipulating financial reporting. The company, which re-mained closely controlled by the Tanzi family through a pyramidal ownership structure afterit went public in 1990, was accused of deliberately exaggerating its earnings. The company’sfounder and CEO, Calisto Tanzi, who admitted to diverting about $640 million from Parmalatto his family’s companies (Sylvers [2004]), was eventually convicted and sentenced. Other in-siders later confessed to depriving outside investors by tunneling “commissions” to offshorecompanies that they controlled (e.g., Gumbel [2004]). After recounting how Mr Tanzi devel-oped connections with politicians, Ferrarini and Giudici [2005, p. 12] argue that, “Parmalatreveals some features common to firms that have faced catastrophic financial failures: mas-sive growth, questionable accounting and accountants, poor underlying performance, polit-ical connections, a dominating shareholder, complex corporate structures and operationalmystery.”
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stakes, providing them with greater incentives and means to siphon corpo-rate resources than their counterparts in independent firms (e.g., La Porta,Lopez-de-Silanes, and Shleifer [1999], Claessens et al. [2000], Bae, Kang,and Kim [2002]). Firms belonging to business groups may be more likelyto appoint a Big 4 auditor to provide outside investors with more assurancethat they abstain from extracting private benefits. Since the separation ofcash flow rights from voting rights in firms affiliated with a business groupmagnifies agency costs, minority investors will particularly value the pres-ence of a Big 4 auditor in this situation. In our second prediction, we ex-amine whether the importance of political connections to auditor choicevaries with firms’ ownership structures:
H2: In comparison to other connected firms, politically connected firmswith ownership characteristics that worsen agency conflicts with out-side investors are even more likely to appoint Big 4 auditors.
2.3 THE MEDIATING ROLE OF COUNTRY-LEVEL INSTITUTIONS
Next, we evaluate whether country-level governance institutions mediatethe relation between auditor choice and political connections. Recent ev-idence implies that political connections are prevalent in countries withunderdeveloped legal institutions and pervasive corruption (e.g., Faccio[2006, 2010]). Reflecting the importance of transparency, Djankov et al.[2010] report that public disclosure of politicians’ finances and businessactivities correlates with lower perceived corruption. Similarly, Johnsonet al. [2000] document that the risk of insider diversion is increasing incountries’ corruption. More recently, Boubakri et al. [2012] find that po-litical connections are more valuable in countries with weak institutionalenvironments. Consequently, we expect that operating in countries withworse institutional infrastructure intensifies connected firms’ incentives toengage a Big 4 auditor to lend more credibility to their financial statements.In our third prediction, we isolate whether the role that political ties playin auditor choice hinges on the quality of countries’ governance institu-tions:
H3: In comparison to other public firms, politically connected firms incountries with relatively poor governance institutions are even morelikely to appoint Big 4 auditors.
2.4 ECONOMIC IMPLICATIONS OF AUDITOR CHOICE IN POLITICALLYCONNECTED FIRMS
Finally, we examine several economic outcomes to help empirically clar-ify what is behind any evidence that political connections elicit greater de-mand for Big 4 auditors. Since exploiting connections to orchestrate thediversion of corporate resources requires hiding, credible financial report-ing plays a natural role in protecting outside investors by lowering infor-mation asymmetry. Accordingly, we predict that connected firms intent onreducing agency costs by appointing a Big 4 auditor exhibit less earnings
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T A B L E 1Politically Connected Firms’ Distribution by Country
Country N % Country N %
Austria 5 0.36 Italy 37 2.70Belgium 20 1.46 Japan 100 7.29Canada 5 0.36 Korea, South 25 1.82Chile 10 0.73 Malaysia 268 19.55Denmark 10 0.73 Mexico 20 1.46Finland 10 0.73 Philippines 18 1.31France 51 3.72 Singapore 54 3.94Germany 28 2.04 Spain 10 0.73Greece 5 0.36 Sweden 10 0.73Hong Kong 22 1.60 Switzerland 15 1.09India 5 0.36 Taiwan 5 0.36Indonesia 105 7.66 Thailand 93 6.78Ireland 10 0.73 United Kingdom 395 28.81Israel 10 0.73 United States 25 1.82
Total 1,371 100
This table reports the country and industry distribution for the sample of 1,371 politically connectedfirms from 28 countries.
management, enabling them to enjoy greater transparency, lower equityfinancing costs, and higher valuations:
H4: In comparison to other politically connected firms, politically con-nected firms with Big 4 auditors benefit from lesser earnings man-agement, greater transparency, higher valuations, and cheaper equityfinancing.
3. Data Description
3.1 THE SAMPLE
To analyze the impact of political connections on auditor choice, wehand-match data from two sources: political connections data from Faccio[2006] and auditor identity, financial statement, and ownership data fromWorldscope. We confine the analysis to countries with connected firms ac-cording to Faccio [2006], which yields a sample of 1,371 (30,181) firm-yearobservations with (without) political connections from 28 countries cover-ing the period from 2001 to 2005.8 Table 1 presents sample characteristicsfor the politically connected firms by country. It is evident from the countrydistribution that the sample exhibits good diversification across geograph-ical regions, including Asia, Europe, Latin America, and North America,
8 However, all of our inferences hold when we extend our analysis to cover the entire setof 47 countries studied in Faccio [2006]. In this expanded sample, politically connected firmsrepresent almost 2% of the total firm-year observations, which is comparable to the 2.7%reported in Faccio’s [2006] full data set.
116 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
which is important when examining the interplay between political connec-tivity and country-level governance institutions. The United Kingdom andMalaysia contribute the largest share of the sample at 28.8% and 19.6%,respectively, followed by Indonesia (7.7%), Japan (7.3%), and Thailand(6.8%). All other countries comprise less than 4% of the sample.
3.2 VARIABLES AND DESCRIPTIVE STATISTICS
3.2.1. Measuring Auditor Quality. We follow extensive prior research bygauging auditor quality with a dummy variable labeled BIG 4 that takes thevalue of one for firms with Big 4 auditors (and their predecessors), andzero otherwise.9 Given that the Worldscope database does not provide au-ditor history details, we ensure accuracy in coding BIG 4 by identifying audi-tors with five (2001–2005) of its compact discs. The descriptive statistics intable 2 reveal that connected firms rely more on Big 4 auditors compared tononconnected firms; the 82–77% difference in market share is statisticallysignificant at the 1% level. The Big 4 market share in our sample is slightlyhigher than the 71% reported in Choi and Wong [2007] for a sample ofpublic firms from 39 countries for the period 1993–1998 and the 74% re-ported in Francis and Wang [2008] for a sample of firms from 42 countriesfor the period 1994–2004. Table A1 summarizes all variables used in theanalysis, including the data sources.
3.2.2. Measuring Political Connections. We rely on Faccio’s [2006] data-base to measure political connections. Faccio [2006, p. 369] explains thata firm is considered politically connected if “at least one of its large share-holders (anyone controlling at least 10% of voting shares) or one of itstop officers (CEO, president, vice-president, chairman, or secretary) is amember of parliament, a minister, or is closely related to a top politician orparty.” Apart from its extensive country coverage, an important upside ofthis database is its considerable detail on the type of connection (i.e., con-nection with members of parliament, a minister or the head of state, and
9 After prior cross-country research analyzing years surrounding its collapse (e.g., Francisand Wang [2008]), we include Arthur Andersen in our main specification of the Big 4 audi-tors. However, our core results remain when we remove all Andersen clients from the estima-tions. Similarly, none of our inferences are sensitive to also excluding the successor auditors(whether Big 4 or non–Big 4) to Andersen after its dissolution in 2002. Another issue is the im-pact on our evidence of potential Worldscope auditor coding errors, which might be evidentin low Big 4 audit market shares in some of the countries represented in our sample. We helpmitigate this concern by removing in successive regressions firms from countries in which theBig 4 market share is below 25% (this involves excluding firms from India and Greece) and50% (this involves excluding firms from India, Greece, France, and Mexico). Our evidencesupporting the prediction in H1 holds at the 5% level or better in these smaller samples. Also,we perform spot checks on 10% of the Indian, Greek, French, and Mexican firms in our sam-ple, which confirms without exception that auditor identity in Worldscope matches that infirms’ annual reports. In any event, auditor coding errors, which inject noise into the analysis,would likely work against our tests rejecting the null hypotheses.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 117
T A B L E 2Descriptive Statistics for the Politically Connected Firms
Means Medians
Connected Nonconnected Connected NonconnectedFirms Firms t-statistics Firms Firms z-statistics
BIG 4 0.82 0.77 3.39∗∗∗
LARGEOWN 0.27 0.26 0.57 0.20 0.17 0.89COMPLEXITY 2.74 2.60 3.08∗∗∗ 3.00 2.00 2.68∗∗∗
FOREIGNSALES 20.46 18.06 2.22∗∗ 0.00 0.00 2.05∗∗
FINANCING 0.07 0.08 –0.99CROSS-LISTING 0.10 0.05 5.48∗∗∗
SIZE 15.68 15.42 2.18∗∗ 15.15 15.50 2.25∗∗
STATEOWN 0.26 0.06 2.06∗∗ 0.00 0.00 1.94∗
ROA 0.03 0.03 1.21 0.04 0.03 0.89LEVERAGE 0.59 0.44 6.59∗∗∗ 0.34 0.18 7.31∗∗∗
GROWTH 4.85 6.30 –2.36∗∗ 3.25 2.88 1.34INV 0.09 0.10 –4.91∗∗∗ 0.06 0.08 –5.36∗∗∗
MTB 1.70 1.61 1.93∗ 1.27 1.20 1.53ACCURACY −0.01 −0.01 0.52 0.00 0.00 0.70IAS 0.18 0.16 1.67∗
ANALYSTS 10.91 8.33 5.63∗∗∗ 10.00 6.00 6.62∗∗∗
EM 0.04 0.08 −4.20∗∗∗ 0.04 0.05 −3.84∗∗∗
KMED 11.15 11.76 −0.76 10.34 10.83 −0.38
This table reports measures of central tendency for all explanatory variables according to political con-nection. The full sample includes 1,371 politically connected firms and 1,911 nonconnected firms. ∗∗∗, ∗∗,and ∗ denote statistical significance at the 1%, 5%, and 10% levels, respectively. Definitions and data sourcesfor the variables are provided in table A1.
close relationship to a top official). Faccio [2006] classifies a firm as con-nected through a minister or head of state when the politician or a close rel-ative (son or daughter) holds this office and is a large shareholder or top of-ficer. In her analysis, a firm is connected with a member of parliament whenthe large shareholder or the top director is a member of parliament. Rela-tives are not included in this classification. Close connections in the formof well-known friendships and connections are identified by several sources(The Economist, Forbes, or Fortune) and prior studies (e.g., Backman [1999],Agrawal and Knoeber [2001], Fisman [2001]). The names of top officersand shareholders are drawn from Worldscope, Extel, Lexis-Nexis, and com-pany Web sites. Shareholder information is also collected from Claessens etal. [2000], Faccio and Lang [2002], and various stock exchanges Web sites.Applying these definitions, Faccio [2006] identifies 541 firms with politicalconnections. We follow recent research by specifying our main test variableas a dummy variable (CONNECTED) that takes the value of one if a companyis identified as politically connected in Faccio’s [2006] database, and zerootherwise (e.g., Faccio, Masulis, and McConnell [2001], Boubakri, Cosset,and Saffar [2008], Boubakri et al. [2012], Faccio [2010], Chaney, Faccio,and Parsley [2011]).
3.2.3. Measuring Country-Level Governance Institutions. We rely on fourwidely used proxies to calibrate the quality of countries’ governance
118 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
institutions. The first variable is Faccio’s [2006, p. 373] regulatory score(RESTRICTIONS), which is an assessment of the stringency of “regulationsthat prohibit or set limits on the business activities of public officials.” Thisregulatory score varies from zero to six with high values indicating majorrestrictions on public officials. The second variable is La Porta et al.’s [1998,p. 1125] measure of the risk of expropriation (EXPROPRIATION), which isan assessment of the “risk of a modification in a contract taking the formof a repudiation, postponement, or scaling down” due to “budget cutbacks,indigenization pressure, a change in government, or a change in govern-ment economic and social priorities.” We recode the index from 0 to 10with higher values reflecting greater risk of expropriation. The third vari-able is Djankov et al.’s [2008] anti-self-dealing index (ANTISELF), whichfocuses on the regulation of corporate self-dealing transactions in 72 coun-tries along three dimensions: disclosure, approval procedures for transac-tions, and facilitation of private litigation when self-dealing is suspected.The fourth proxy is La Porta, Lopez-de-Silanes, and Shleifer’s [2006] mea-sure of investor protection (PROTECTION), which is equal to the princi-pal component of the anti-director rights, disclosure requirements, and li-ability standards indices described in their database. Table A2 reports themeans of these variables by country.
3.2.4. Control Variables. In our multivariate regression analysis, we at-tempt to isolate the role that political connections play by comprehen-sively controlling for two sets of variables known to affect auditor choiceaccording to prior research (e.g., Mansi, Maxwell, and Miller [2004], Fanand Wong [2005], Lennox [2005], Choi and Wong [2007], Fortin andPittman [2007], Wang, Wong, and Xia [2008], Guedhami, Pittman, andSaffar [2009]). The first set includes the following firm-level characteristics:firm size (SIZE), which we measure with the natural logarithm of total as-sets expressed in U.S. dollars;10 asset structure (INV), which we capture withthe ratio of inventory to total assets; leverage (LEVERAGE), which we codeas the ratio of long-term debt to total equity; growth (GROWTH), whichamounts to the asset growth ratio in the past year; ownership structure vari-ables: the equity stakes held by the largest shareholder (LARGEOWN) andthe government (STATEOWN), and the percentage of voting rights belong-ing to the ultimate owner (CONTROLRIGHTS) obtained from Claessens,Djankov, and Lang [2000] and Faccio and Lang [2002]; complexity
10 None of our core results are materially sensitive to replacing SIZE with the natural loga-rithm of sales or market capitalization. Given that both BIG 4 and POLITICAL are positivelycorrelated with SIZE according to table A3, we help reduce the concern that firm size is spu-riously responsible for our evidence as follows. After Feltham, Hughes, and Simunic [1991]and Pittman and Fortin [2004], we re-estimate our regressions after isolating a size-truncatedsample comprised of all firms ranging between the smallest Big 4 client according to assetsand the largest non–Big 4 client. In this restricted sample, which helps address whether ourresults reflect pervasive economic phenomena rather than very large firms dominating theanalysis, the evidence on our predictions persists at the 5% level or better.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 119
(COMPLEXITY), which we measure with the number of business segmentsbased on two-digit SIC codes; foreign sales (FOREIGNSALES), which is theportion of sales from foreign operations; level of financing activities, whichwe capture with two variables: a dummy variable that takes the value of oneif the sum of new long-term debt plus new equity exceeds 20% of total as-sets (FINANCING) and cross-listing in foreign markets (CROSS-LISTING);and profitability (ROA), which is the return on assets ratio. The second setof controls includes two macroeconomic variables, namely the logarithmof GDP per capita (LGDPC) and a country’s foreign direct investment as afraction of GDP (FDI), and a proxy for a country’s auditor discipline infras-tructure, which reflects the intensity of civil litigation against auditors (SUEAUDITOR) according to La Porta, Lopez-de-Silanes, and Shleifer [2006].Prior evidence suggests a high correlation between the level of economicdevelopment and the demand for transparency, including auditor choice(e.g., Leuz, Nanda, and Wysocki [2003], Guedhami, Pittman, and Saffar[2009]).
Table 2 presents descriptive statistics for the regression variables. Theaverage politically connected firm in our sample is relatively large accord-ing to its assets (SIZE = 15.7; $553 million before logarithmic transforma-tion) and valuable (MTB = 1.7), with considerable long-term debt to equity(LEVERAGE = 59%) and moderate asset growth (GROWTH = 5%) and for-eign operations (FOREIGNSALES = 20%). In comparison to nonconnectedfirms, we find that connected firms, on average, are larger, more leveraged,more complex, and more likely to cross-list in foreign markets. Althoughconnected firms have a higher fraction of state ownership and foreign salesthan nonconnected firms, their growth rates and inventory levels tend to belower. These differences are consistent with prior research (e.g., Boubakri,Cosset, and Saffar [2008], Boubakri et al. [2012], Faccio [2010]).
Table A3 reports correlation coefficients between the regression variableswhile allowing for country and firm level clustering. Consistent with theprediction in H1, we observe a positive correlation between CONNECTEDand BIG 4 that is significantly different from zero at the 1% level. In thenext section, we consider whether this preliminary evidence that politicallyconnected firms are more likely to appoint Big 4 auditors persists in a seriesof multivariate regressions. Finally, we find that the correlations betweenthe controls are generally small, reducing concerns that multicollinearity isspuriously responsible for our evidence on the predictions.
4. Empirical Results
In a multivariate regression framework, we estimate the impact of polit-ical connections on the likelihood that firms will hire a Big 4 auditor toexamine the prediction in H1. Next, we analyze the prediction in H2 thatagency problems embedded in firms’ ownership structures strengthen thelink between political connections and auditor choice. For the predictionin H3, we isolate whether the importance of political connections to auditor
120 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
choice hinges on the quality of a country’s governance institutions. Finally,we examine whether politically connected firms with Big 4 auditors benefitfrom lower earnings management, greater transparency, higher valuations,and cheaper financing under the prediction in H4.
4.1 POLITICAL CONNECTIONS AND AUDITOR CHOICE
4.1.1. Main Evidence. To evaluate the link between political connectionsand auditor choice, we focus on the sample of connected firms describedin section 3.1 and a set of peer firms without political connections. In or-der to improve identification by confronting the threat that differences infirm characteristics, such as their ownership structures and size, are spu-riously responsible for any evidence supporting our predictions, we em-ploy two separate matching techniques to specify the benchmark group ofnonconnected firms.11 The first peer group consists of nonconnected firmsmatched to connected firms based on country, industry, year, and decile oftotal assets. The second group comprises firms matched on various observ-able characteristics according to a propensity score matching procedurethat we outline below.
Table 3 presents the results from estimating several pooled multivariatelogistic regressions to analyze the impact of political connections on au-ditor choice worldwide. All standard errors are clustered at the firm andcountry level, and adjusted for heteroskedasticity. We rely on two-sidedtests to gauge statistical significance in all estimations. To better assess theeconomic impact of the key test variable (CONNECTED), we also reportmarginal effects in square brackets. In these regressions, we control forownership structure in alternative ways. In models 1 and 2, we control forthe equity stake of the largest shareholder (LARGEOWN), rather than theirultimate ownership (CONTROLRIGHTS), to reduce data attrition. For ex-ample, narrowing our focus to firms with ultimate ownership data wouldlower the countries under study from 28 to 19, preventing us from exam-ining firms from countries such as the United States and Mexico that havea considerable number of political connections according to table 1. How-ever, we replace LARGEOWN with CONTROLRIGHTS in models 3 and 4and with both CONTROLRIGHTS and CASHFLOWRIGHTS in models 5 and6 to better isolate the incremental importance of political connections toauditor choice beyond the ultimate ownership effects that Fan and Wong[2005] document.
Model 1 reveals that the coefficient for the dummy variable identifyingpolitically connected firms (CONNECTED) loads positively at the 5% level,implying that these firms are more likely to hire Big 4 auditors relative tononconnected peers in the same country, industry, year, and decile of total
11 In another strategy for isolating the importance of political connections to auditorchoice, we assemble a third peer group consisting of nonconnected peers matched to con-nected firms based on country, industry, and year. In unreported estimations, we find evidenceat the 1% level supporting the prediction in H1 when we apply this matching technique.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 121
TA
BL
E3
Polit
ical
Con
nect
ions
and
the
Aud
itor
Cho
ice
Full
Sam
ple
Ult
imat
eO
wn
ersh
ipSa
mpl
e
Con
nec
ted
Firm
sM
atch
edPr
open
sity
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nec
ted
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sM
atch
edPr
open
sity
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nec
ted
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sM
atch
edPr
open
sity
onC
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try,
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stry
,Yea
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ore
onC
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try,
Indu
stry
,Yea
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ore
onC
oun
try,
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stry
,Yea
r,Sc
ore
and
Dec
ileof
Tota
lAss
ets
Mat
chin
gan
dD
ecile
ofTo
talA
sset
sM
atch
ing
and
Dec
ileof
Tota
lAss
ets
Mat
chin
g
Mod
els
12
34
56
CO
NN
ECT
ED0.
41∗∗
0.32
∗0.
54∗∗
0.36
∗∗0.
53∗∗
0.36
∗∗
(2.5
2)(1
.78)
(2.4
8)(2
.06)
(2.4
5)(2
.05)
LA
RG
EOW
N0.
67∗
−0.1
7(1
.78)
(−0.
47)
CO
NT
RO
LR
IGH
TS
−1.3
0∗∗∗
0.24
−1.2
2∗∗0.
31(−
2.66
)(0
.62)
(−2.
34)
(0.4
9)C
ASH
FLO
WR
IGH
TS
−0.1
9−0
.09
(−0.
42)
(−0.
15)
CO
MPL
EXIT
Y−0
.11∗
−0.0
50.
02−0
.01
0.02
−0.0
1(−
1.76
)(−
0.78
)(0
.23)
(−0.
15)
(0.2
3)(−
0.14
)FO
REI
GN
SAL
ES0.
01∗∗
∗0.
000.
01∗∗
0.00
0.01
∗∗0.
00(3
.02)
(0.8
2)(2
.36)
(0.2
3)(2
.33)
(0.2
2)FI
NA
NC
ING
0.01
−0.2
20.
15−0
.27
0.15
−0.2
7(0
.07)
(−1.
17)
(0.5
5)(−
1.49
)(0
.54)
(−1.
49)
CR
OSS
-LIS
TIN
G0.
620.
440.
83∗∗
0.49
0.82
∗∗0.
48(1
.47)
(0.9
5)(2
.08)
(1.0
5)(2
.05)
(1.0
5)SI
ZE0.
15∗∗
∗0.
21∗∗
∗0.
10∗∗
∗0.
20∗∗
∗0.
10∗∗
∗0.
20∗∗
∗
(6.2
5)(6
.87)
(3.3
9)(6
.44)
(3.4
0)(6
.34)
RO
A2.
08∗∗
∗0.
74∗
1.95
∗∗∗
0.61
1.97
∗∗∗
0.61
(4.0
9)(1
.75)
(2.7
1)(1
.46)
(2.7
5)(1
.46)
STAT
EOW
N−0
.05∗∗
∗−0
.06∗∗
−0.0
2−0
.06∗∗
−0.0
2−0
.06∗∗
(−3.
60)
(−2.
30)
(−0.
40)
(−2.
38)
(−0.
41)
(−2.
38)
LEV
ERA
GE
−0.0
5−0
.10
0.01
−0.0
80.
01−0
.08
(−0.
46)
(−0.
87)
(0.0
9)(−
0.70
)(0
.07)
(−0.
70)
(Con
tinue
d)
122 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
TA
BL
E3—
Con
tinue
d
Full
Sam
ple
Ult
imat
eO
wn
ersh
ipSa
mpl
e
Con
nec
ted
Firm
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atch
edPr
open
sity
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ted
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atch
edPr
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atch
edPr
open
sity
onC
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ore
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ileof
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sset
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atch
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and
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ileof
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lAss
ets
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chin
g
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OW
TH
−0.0
1∗∗∗
−0.0
0−0
.00
−0.0
0−0
.00
−0.0
0(−
2.84
)(−
0.16
)(−
0.21
)(−
0.55
)(−
0.23
)(−
0.56
)IN
V−1
.19∗
−0.9
6−1
.93∗∗
−0.7
5−1
.92∗∗
−0.7
5(−
1.69
)(−
1.37
)(−
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)(−
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)(−
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)(−
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)FD
I0.
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∗0.
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∗0.
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∗0.
010.
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∗
(3.4
1)(2
.97)
(0.2
7)(2
.82)
(0.3
0)(2
.82)
LG
DPC
0.33
∗∗∗
0.42
∗∗∗
0.17
∗∗0.
45∗∗
∗0.
17∗
0.45
∗∗∗
(4.5
8)(5
.41)
(2.0
3)(5
.61)
(1.9
1)(5
.62)
SUE
AU
DIT
OR
1.05
∗∗∗
1.12
∗∗∗
1.66
∗∗∗
1.10
∗∗∗
1.64
∗∗∗
1.09
∗∗∗
(2.7
3)(3
.32)
(3.4
3)(3
.18)
(3.4
0)(3
.17)
Inte
rcep
t−4
.99∗∗
∗−6
.43∗∗
∗−2
.80∗∗
−6.8
1∗∗∗
−2.7
1∗∗−6
.82∗∗
∗
(−5.
91)
(−6.
42)
(−2.
43)
(−6.
45)
(−2.
31)
(−6.
45)
[Mar
gin
alef
fect
ofC
ON
NEC
TED
in%
]
[6.1
1][5
.37]
[7.6
9][6
.28]
[7.6
0][6
.25]
Pseu
doR
20.
100.
110.
090.
110.
090.
10χ
215
3.8
132.
190
.37
119.
390
.57
119.
4N
3,28
22,
742
2,69
02,
266
2,69
02,
266
Th
ista
ble
repo
rts
pool
edlo
git
esti
mat
ion
resu
lts
for
audi
tor
choi
ceof
polit
ical
lyco
nn
ecte
dfi
rms
and
non
con
nec
ted
firm
s.T
he
sam
ple
con
sist
sof
1,37
1po
litic
ally
con
nec
ted
firm
san
dth
ese
tof
peer
firm
sw
ith
out
polit
ical
con
nec
tion
sm
atch
edto
con
nec
ted
firm
sba
sed
onco
untr
y,in
dust
ry,y
ear,
and
deci
leof
tota
lass
ets
(mod
els
1,3,
and
5)an
dva
riou
sob
serv
able
char
acte
rist
ics
acco
rdin
gto
apr
open
sity
scor
em
atch
ing
proc
edur
e(m
odel
s2,
4,an
d6)
.Ben
eath
each
esti
mat
eis
repo
rted
the
robu
stz-
stat
isti
ccl
uste
red
atbo
thth
eco
untr
yan
dth
efi
rmle
vel.
Th
eta
ble
also
repo
rts
the
mar
gin
alef
fect
ofth
eva
riab
leC
ON
NEC
TED
.∗∗
∗ ,∗∗
,an
d∗
den
ote
stat
isti
cal
sign
ifica
nce
atth
e1%
,5%
,an
d10
%le
vels
,re
spec
tive
ly,b
ased
ontw
o-si
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test
s.T
he
defi
nit
ion
san
dda
taso
urce
sfo
rth
eva
riab
les
are
outl
ined
inta
ble
A1.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 123
assets.12 Reflecting its material economic impact, the coefficient estimatefor CONNECTED translates into political affiliations increasing the likeli-hood of appointing a Big 4 auditor by 6%, with all other variables assignedtheir mean values. This result is consistent with the prediction in H1 thatpolitically connected firms are associated with greater demand for Big 4auditors.13
Next, we examine the demand for a Big 4 auditor between connectedfirms and nonconnected peers matched according to propensity scores de-rived as follows (e.g., Boubakri et al. [2012]). First, we require that thecandidate firm for the matching share the same country, year, and indus-try class as the connected firm. Second, among the potential control samplefirms, we select the optimal match based on the nearest neighbor techniqueof the propensity score matching procedure. We follow Rosenbaum andRubin [1983] and Heckman, Ichimura, and Todd [1997, 1998] in relyingon this procedure in an attempt to control for differences in characteristicsbetween connected and nonconnected firms. To calculate the propensityscore, we analyze a comprehensive set of firm characteristics that shouldcapture the likelihood that a given firm will be politically connected ac-cording to prior research. More specifically, we consider size, leverage, thelargest shareholder’s ownership stake, state ownership, and cross-listing asconnected firms are likely to be different from nonconnected peers alongthese characteristics (see, e.g., Faccio [2006, 2010], Leuz and Oberholzer-Gee [2006], Boubakri, Cosset, and Saffar [2008], and Bunkanwanicha andWiwattanakantang [2009]).
This matching procedure translates into a sample of 2,742 firm-year ob-servations equally distributed by country, industry, and year between polit-ically connected and nonconnected firms. Despite the major data attritionthat accompanies constructing a matched sample using propensity scores inour setting, an upside of applying this technique here is the large numberof potential matches (30,181 nonconnected observations), ensuring thatthe connected and nonconnected samples have extremely close propen-sity scores. In model 2, we find that connected firms are significantly more
12 Reflecting the importance of political connections to auditor choice, the incremental R 2
for CONNECTED is 0.037 relative to 0.027 for SIZE.13 Although we follow extensive prior research in primarily specifying auditor quality with
the presence or absence of a Big 4 auditor, we also examine whether our results are mate-rially sensitive to replacing BIG 4 with firms’ audit fees. Extant research implies that auditfees are higher when auditors expend more effort on an engagement, translating into bet-ter audits (e.g., Dye [1993], Davis, Ricchiute, and Trompeter [1993], Whisenant, Sankaragu-ruswamy, and Raghunandan [2003], Caramanis and Lennox [2008]). Consequently, politi-cally connected firms will incur higher audit fees under the intuition for the prediction inH1. However, given poor audit fee data availability in Worldscope, the sample shrinks to 1,756firm-year observations compared to the 3,282 observations under study in model 1 in table 3.Nevertheless, we find in unreported results that CONNECTED continues to load positively atthe 1% level despite the loss in power in this smaller sample, suggesting that connected firmspay higher audit fees than their nonconnected peers matched by country, industry, year, andsize.
124 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
likely to appoint a Big 4 auditor than their propensity score matched peers.The coefficient estimate for CONNECTED in model 2 implies that a 5%increase in the probability of engaging a Big 4 auditor accompanies a polit-ical connection. In unreported tests, we exploit the large number of closematches available in our data set by implementing one-to-five and one-to-ten matching, and find that CONNECTED loads positively at the 5% and 1%levels, respectively, in these larger samples.
To better isolate the impact of political connections on auditor choice,we replace in models 3 and 4 the variable LARGEOWN with the ultimateownership variable CONTROLRIGHTS after Fan and Wong [2005]. In bothregressions, we continue to estimate a positive and statistically significant(at the 5% level) coefficient on CONNECTED. Corroborating our earlierevidence, these results imply that connected firms are more likely to en-gage a Big 4 auditor compared to their peer group of nonconnected firms.Economically, the coefficient estimates for CONNECTED suggest that firmsbecome 8% (model 3) and 6% (model 4) more likely to hire a Big 4 audi-tor in the presence of a political connection, with all other variables set totheir mean values. We complement the propensity score matching evidencein model 4 by conducting one-to-five and one-to-ten matching to take ad-vantage of the deep pool of control observations available in our data set.In these unreported estimations, we find that CONNECTED is positive andstatistically significant at the 1% level in both cases. In models 5 and 6, wecontinue to find that CONNECTED loads positively at the 5% level when weadd the cash flow rights of the ultimate owner to models 3 and 4. Consistentwith Fan and Wong [2005], CASHFLOWRIGHTS is statistically insignificantin these regression models, while CONTROLRIGHTS only enters negativelyin model 5. It is important to note that these ownership variables are highlycorrelated in our data (ρ = 0.77, p < 0.001).
In other unreported analysis, we follow Fan and Wong [2005] by speci-fying control concentration with a dummy variable (CONTROLRIGHTS ≥30%) assigned the value one if CONTROLRIGHTS is at least 30%, and zerootherwise. Additionally, in successive regressions, we replace CONTROL-RIGHTS with the separation between the voting and cash-flow rights be-longing to the ultimate owner (WEDGE), and a dummy variable set equalto one if WEDGE is at least 20%, and zero otherwise. We find that ourcore evidence on CONNECTED holds at the 5% level or better in thesere-estimations, reinforcing that the importance of political connections toauditor choice is incremental to the impact of the ultimate ownership char-acteristics that Fan and Wong [2005] examine.14
14 Our empirical design primarily diverges from Fan and Wong’s [2005] in two ways. First,we control for a larger set of firm-level determinants of auditor choice. In fact, the 14 controlsfor firm characteristics in our models include the four in their main specifications. Second, weapply various matching techniques to improve identification in our setting. After restrictingour sample to the eight Asian countries analyzed in Fan and Wong [2005] and no longerexamining matched samples, we find a positive and statistically significant coefficient on
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 125
Collectively, the results in table 3 using different matching techniquessuggest that the demand for a Big 4 auditor is higher in politically con-nected firms relative to their nonconnected peers. Importantly, our ev-idence persists after controlling for a comprehensive set of firm-leveldeterminants of auditor choice. In particular, we find that the role thatpolitical connections play in auditor choice extends beyond the impact ofthe ownership variables capturing the equity stakes held by the ultimateshareholder and the state. Interestingly, the coefficient for state ownership(STATEOWN) is generally negative and statistically significant in table 3.This result suggests that the demand for Big 4 auditors is decreasing instate ownership, supporting that the evidence in Guedhami, Pittman, andSaffar [2009] for the specific case of newly privatized firms generalizes topublic firms worldwide. More generally, this evidence squares with prior re-search on the political economy and financial reporting transparency (e.g.,Bushman, Piotroski, and Smith [2004], Bushman and Piotroski [2006]).Among the other firm-level determinants, we find that firm size, profitabil-ity, and foreign sales are positively related to auditor choice; only FINANC-ING and LEVERAGE have no perceptible impact on this decision in any ofthe table 3 regressions. Additionally, the three country-level controls (FDI,LGDPC, and SUE AUDITOR) generally enter positively and significantly atthe 5% level or better, implying that the demand for high-quality auditorsis higher in countries with more foreign investor involvement, more devel-oped economies, and more discipline imposed on auditors through civillitigation institutions.
4.1.2. Sensitivity Analyses. In this section, we evaluate whether our ear-lier evidence on the importance of political connections to auditor choicepersists when we tackle potential omitted variables bias and endogeneity,re-estimate our regressions on alternative matched samples, and respecifyauditor quality. To preview, the results that we report in table 4 lend ad-ditional support to the prediction in H1 that public firms with politicalconnections are more likely to appoint high-quality auditors. Except whenexamining whether our evidence holds when we apply alternative matchingapproaches, we rely on the sample of connected firms and nonconnectedpeers matched based on country, industry, year, and decile of total assets(model 3 in table 3) as our baseline in these sensitivity tests.
4.1.2.1. Omitted Variables Bias and Endogeneity. We begin the sensitivityanalysis by confronting whether endogeneity or omitted variables bias ex-plains the evidence in table 3. Although our research design mitigatesthese issues since we control for an extensive set of firm- and country-level
CONTROLRIGHTS, helping to reconcile our evidence to theirs. More generally, our resultsare consistent with El Ghoul et al. [2013], who find that Fan and Wong’s [2005] evidencefor East Asia does not extend to Western Europe where investor protection institutions aretypically better.
126 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFART
AB
LE
4Po
litic
alC
onne
ctio
nsan
dth
eA
udito
rC
hoic
e:Se
nsiti
vity
Test
s
Ran
dom
Eff
ects
Add
itio
nal
Con
trol
Vari
able
s
Exc
lude
Shor
tA
udit
orTe
nur
e
Con
nec
ted
Firm
sM
atch
edon
Cou
ntr
y,In
dust
ry,Y
ear,
and
Dec
ileof
the
Lar
gest
Shar
ehol
der’
sVo
tin
gR
igh
ts
Con
nec
ted
Firm
sM
atch
edon
Cou
ntr
y,In
dust
ry,Y
ear,
and
Lar
gest
Ow
ner
Iden
tity
Mod
els
12
34
5C
ON
NEC
TED
1.74
∗∗0.
59∗∗
1.00
∗∗∗
0.56
∗∗0.
54∗∗
(2.4
4)(2
.13)
(3.0
7)(2
.36)
(2.4
8)C
ON
TR
OL
RIG
HT
S−4
.92∗∗
∗−0
.50
−1.0
2∗−1
.21∗∗
−1.3
0∗∗∗
(−2.
93)
(−0.
87)
(−1.
74)
(−2.
08)
(−2.
66)
CO
MPL
EXIT
Y−0
.00
0.03
−0.0
1−0
.02
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(−0.
00)
(0.3
7)(−
0.16
)(−
0.25
)(0
.23)
FOR
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LES
0.01
0.01
∗0.
01∗∗
0.01
∗0.
01∗∗
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4)(1
.92)
(2.3
2)(1
.71)
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6)FI
NA
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ING
1.61
∗∗0.
300.
120.
460.
15(1
.99)
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1)(0
.34)
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6)(0
.55)
CR
OSS
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TIN
G2.
35∗
0.87
∗∗1.
49∗∗
1.09
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83∗∗
(1.8
3)(2
.15)
(2.1
9)(1
.91)
(2.0
8)SI
ZE0.
27∗∗
∗0.
23∗∗
∗0.
10∗∗
0.12
∗∗∗
0.10
∗∗∗
(2.8
9)(4
.44)
(2.5
1)(3
.45)
(3.3
9)ST
ATEO
WN
−0.0
1−0
.02
0.01
0.01
−0.0
2(−
0.04
)(−
0.49
)(0
.14)
(0.0
9)(−
0.40
)R
OA
3.24
∗2.
08∗∗
∗1.
80∗∗
2.49
∗∗∗
1.95
∗∗∗
(1.6
6)(2
.83)
(2.0
6)(2
.66)
(2.7
1)L
EVER
AG
E0.
030.
030.
24−0
.12
0.01
(0.1
0)(0
.24)
(1.4
6)(−
0.76
)(0
.09)
GR
OW
TH
−0.0
0−0
.00
−0.0
0−0
.00
−0.0
0(−
0.33
)(−
1.06
)(−
0.62
)(−
0.22
)(−
0.21
)IN
V−7
.96∗∗
∗−0
.65
−2.4
0∗∗∗
−1.8
6∗−1
.93∗∗
(−3.
50)
(−0.
76)
(−2.
61)
(−1.
92)
(−2.
47)
FDI
−0.1
0∗∗−0
.04∗
0.01
0.02
0.01
(−2.
25)
(−1.
95)
(0.3
5)(0
.61)
(0.2
7) (Con
tinue
d)
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 127T
AB
LE
4—C
ontin
ued
Ran
dom
Eff
ects
Add
itio
nal
Con
trol
Vari
able
s
Exc
lude
Shor
tA
udit
orTe
nur
e
Con
nec
ted
Firm
sM
atch
edon
Cou
ntr
y,In
dust
ry,Y
ear,
and
Dec
ileof
the
Lar
gest
Shar
ehol
der’
sVo
tin
gR
igh
ts
Con
nec
ted
Firm
sM
atch
edon
Cou
ntr
y,In
dust
ry,Y
ear,
and
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gest
Ow
ner
Iden
tity
LG
DPC
0.44
−0.5
70.
030.
21∗∗
0.17
∗∗
(1.6
2)(−
1.34
)(0
.26)
(2.0
4)(2
.03)
SUE
AU
DIT
OR
8.37
∗∗∗
2.16
∗∗2.
06∗∗
∗1.
51∗∗
1.66
∗∗∗
(4.8
0)(2
.40)
(3.3
9)(2
.40)
(3.4
3)O
PEN
NES
S0.
01∗∗
∗
(2.6
0)N
EWSP
APE
R0.
36(1
.08)
DIS
CL
OSE
1.71
(1.5
7)JU
DIC
IAL
−0.1
4(−
0.95
)R
UL
EOFL
AW0.
14(0
.48)
PRED
ATIO
N−0
.95∗∗
∗
(−4.
53)
BU
SIN
ESSG
RO
UP
−0.3
2(−
1.10
)In
terc
ept
−4.7
8−0
.51
−1.4
7−3
.31∗∗
−2.8
0∗∗
(−1.
34)
(−0.
27)
(−1.
00)
(−2.
43)
(−2.
43)
[Mar
gin
alef
fect
ofC
ON
NEC
TED
in%
]−
[8.1
6][9
.84]
[7.9
8][7
.69]
Pseu
doR
2−
0.14
0.11
0.09
0.09
χ2
−11
6.1
67.8
967
.35
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7N
2,69
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2,11
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144
2,69
0
Th
ista
ble
repo
rts
pool
edlo
git
esti
mat
ion
resu
lts
for
audi
tor
choi
ceof
polit
ical
lyco
nn
ecte
dfi
rms
and
non
con
nec
ted
firm
sus
ing
the
spec
ifica
tion
inm
odel
3in
tabl
e3
asth
eba
selin
ere
gres
sion
.Mod
el1
uses
pan
elra
ndo
mef
fect
sto
esti
mat
eou
rba
selin
esp
ecifi
cati
on.M
odel
2in
clud
esO
PEN
NES
S,N
EWSP
APE
R,D
ISC
LO
SE,J
UD
ICIA
L,R
UL
EOFL
AW,
PRED
ATIO
N,a
nd
BU
SIN
ESSG
RO
UP
asad
diti
onal
con
trol
vari
able
s.M
odel
3co
nsi
ders
the
sam
ple
ofco
nn
ecte
dfi
rms
that
nei
ther
upgr
ade
from
an
on–B
ig4
toa
Big
4au
dito
rn
ordo
wn
grad
efr
oma
Big
4to
an
on–B
ig4
audi
tor
betw
een
1998
and
2005
(i.e
.,th
em
odel
excl
udes
firm
sw
ith
shor
tau
dito
rte
nur
e).M
odel
4co
nsi
ders
asa
mpl
eof
con
nec
ted
firm
sm
atch
edon
coun
try,
indu
stry
,yea
r,an
dde
cile
ofth
ela
rges
tsh
areh
olde
r’s
voti
ng
righ
ts.M
odel
5co
nsi
ders
asa
mpl
eof
con
nec
ted
firm
sm
atch
edon
coun
try,
indu
stry
,yea
r,an
dth
ela
rges
tsh
areh
olde
r’s
iden
tity
.Ben
eath
each
esti
mat
eis
repo
rted
the
robu
stz-
stat
isti
ccl
uste
red
atbo
thth
eco
untr
yan
dth
efi
rmle
vel.
Th
eta
ble
also
repo
rts
the
mar
gin
alef
fect
ofth
eva
riab
leC
ON
NEC
TED
.∗∗∗ ,
∗∗,a
nd
∗de
not
est
atis
tica
lsig
nifi
can
ceat
the
1%,5
%,a
nd
10%
leve
ls,r
espe
ctiv
ely,
base
don
two-
side
dte
sts.
Th
ede
fin
itio
ns
and
data
sour
ces
for
the
vari
able
sar
eou
tlin
edin
tabl
eA
1.
128 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
variables and implement various matching procedures, we address linger-ing concerns with three techniques.
First, in unreported analysis, we estimate a treatment effects model sinceit is plausible that some unobserved determinants of auditor choice mayalso affect political connections, causing our reported results to be bi-ased and inconsistent. After Chaney, Faccio, and Parsley [2011] and Chen,Chen, and Wei [2011], we rely on CAPITAL—a dummy variable set equalto one if the firm is located in the capital city, and zero otherwise—as aninstrument for political connectivity given prior evidence on its role in facil-itating the formation of political connections (e.g., Roberts [1990], Agrawaland Knoeber [2001], Bertrand et al. [2007]). Importantly, the correlationbetween CAPITAL and BIG 4 is small in our data set (ρ = 0.05), helping tojustify the validity of this exclusion restriction (e.g., Larcker and Rusticus[2010], Lennox, Francis, and Wang [2012]). In the first stage, we performa logit regression of political ties on the dummy variable CAPITAL and theset of independent variables included in model 3 of table 3. The first stagefitted values for political connections are then used in the second stagelogit regression explaining auditor choice. Similar to Boubakri, Cosset, andSaffar [2008] and Chaney, Faccio, and Parsley [2011], the first stage regres-sion results include that the firm’s location is a good predictor of politicalconnections: the coefficient for CAPITAL loads positively at the 1% level,implying that the incidence of connections is higher for firms located inthe capital. Consistent with the prediction in H1, we find in the secondstage logit estimation that the coefficient of the (predicted) political con-nection variable is positive and statistically significant at the 1% level.15
Second, we exploit the panel nature of our data by estimating a randomeffects model. In the results reported in model 1 of table 4, we continue tofind that appointing a Big 4 auditor becomes more likely in the presenceof a political connection. This is constructive for mitigating the concernthat omitted variables are spuriously behind the evidence supporting theprediction in H1. Third, we control for several additional country-level fac-tors that capture: openness to international trade (OPENNESS); the level offreedom of the press (NEWSPAPER), which measures the extent of publicopinion pressure according to Dyck and Zingales [2004]; the risk of state
15 Although the treatment effects model has the advantage of analyzing the entire sample(e.g., Chaney, Faccio, and Parsley [2011]), an alternative approach to addressing endogeneityin order to improve identification is to analyze political connection formation over time andobserve the ensuing effects on auditor choice. However, Chaney, Faccio, and Parsley [2011]stress that a major limitation of this approach is the small sample of firms for which the dateof political connection formation can be determined, preventing researchers from using for-mation dates to draw meaningful inferences. In our setting, we could only pinpoint the dateof formation of the political connection for 44% of our sample. Regrettably, the vast majorityof these connections were forged before 2001 when our sample period begins, precludingus from reliably examining the link between changes in political connections and auditorchoice. Moreover, Faccio’s [2006] database does not disclose the connected member, whichcomplicates tracking shifts in political affiliations over our 2001–2005 sample period.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 129
expropriation (PREDATION) using Durnev and Fauver’s [2009] predationindex; and three proxies for the quality of legal institutions derived from LaPorta, Lopez-de-Silanes, and Shleifer [2006], namely, accounting standards(DISCLOSE), the efficiency of the judicial system (JUDICIAL), and the ruleof law (RULEOFLAW). Prior research implies that these country-level vari-ables matter to the demand for accounting transparency as well as the pres-ence and value of political connections (e.g., Faccio [2006], Choi and Wong[2007], Guedhami, Pittman, and Saffar [2009], Boubakri et al. [2012]).Besides these country-level variables, we control for business group mem-bership (BUSINESSGROUP), which may affect group-wide auditor choice.Despite that adding these controls leads to some sample attrition, we findin model 2 that the positive relation between CONNECTED and auditorchoice remains in this regression. Although these additional tests providesome assurance that endogeneity is not responsible for the link that we ob-serve between political connections and auditor choice, we stress that westill cannot infer causality from the analysis.
It also would be premature to conclude that our evidence reflects thatpolitically connected firms are more likely to appoint a Big 4 auditor toprovide stricter monitoring of the financial reporting process unless weconsider two other competing explanations for our evidence. First, a Big 4auditor can protect its valuable reputation and avoid litigation by refusingto accept engagements from clients that are more apt to resort to manip-ulating their financial statements to hide underlying performance, or re-sign from engagements when the ensuing risk reaches an intolerable level(e.g., DeFond, Ettredge, and Smith [1997], Shu [2000], Johnstone and Be-dard [2004]). Second, insiders intending to materially distort their firms’financial statements by, for example, overstating earnings to conceal theirdiversionary activities may prefer to hire a non–Big 4 auditor in order to flyunder the radar when they begin accumulating private benefits at the ex-pense of outside investors (e.g., Fan and Wong [2005], Guedhami, Pittman,and Saffar [2009]).
We follow Lennox and Pittman [2010] in considering the potential rolesthat screening by auditors and selection by their clients play by evaluat-ing whether our core results hold when we isolate firms with long auditortenure. The intuition for this analysis is that endogeneity is worse when theduration between auditor choice and the decision to deliberately exagger-ate earnings is shorter since a firm planning to misreport would requireless lead time to cover its tracks by switching to a non–Big 4 auditor, whileits Big 4 auditor may shed clients that have become riskier (e.g., Jones andRaghunandan [1998], Johnstone and Bedard [2004]).16 Consequently, werestrict the sample to firms that neither upgrade from a non–Big 4 to a Big 4
16 Consistent with Bockus and Gigler’s [1998] theory, Shu [2000] reports that riskier clientsare less likely to retain another large auditor when their incumbent auditor resigns from theengagement. Although prior research implies that large audit firms in the United States aremore eager to avoid riskier clients since they have more to lose in the form of reputational and
130 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
auditor nor downgrade from a Big 4 to a non–Big 4 auditor between 1998and 2005—this timeframe covers the five years (2001–2005) under studyin the rest of our analysis and the three preceding years—since we are onmore solid ground in treating BIG 4 as predetermined when auditor tenureis longer (Myers, Myers, and Omer [2003], Caramanis and Lennox [2008],Chang, Dasgupta, and Hilary [2009]). In this smaller sample, we find sup-port at the 1% level in model 3 for the prediction in H1, reducing concernthat screening or selection phenomena are spuriously responsible for ourearlier evidence. Our results are almost identical when we apply the samefive-year tenure breakpoint as Lennox and Pittman [2010].
4.1.2.2. Alternative Samples. In recent cross-country research, Guedhami,Pittman, and Saffar [2009] examine auditor choice in state-owned enter-prises and during their transition to private ownership. In particular, theyreport a negative relation between the extent of government ownership andthe likelihood of selecting a Big 4 auditor. They also find that privatizationcorrects the distortions in auditor choice that Wang, Wong, and Xia [2008]stress, although continued government ownership lowers the probability ofappointing a Big 4 auditor after privatization. To alleviate the concern thatour evidence on the role that political connections play in auditor choicereflects the government’s ownership, we control for its equity stake in allregressions. In unreported analysis, we better isolate the importance of po-litical connections to this decision by excluding privatized firms. The pos-itive and statistically significant relation at the 1% level between politicalconnections and auditor choice persists in this regression.
Our empirical strategy in table 3 involves applying two forms of match-ing to improve identification. Next, we expand this analysis to considerwhether our core evidence is robust to implementing alternative match-ing techniques. First, in model 4, we compare connected firms to theirnonconnected peers matched based on country, industry, year, and decileof the largest shareholder’s voting rights. Second, in model 5, we selectnonconnected firms based on country, industry, year, and the largest share-holder’s identity—the specific types reflect ownership by widely held non-financial institutions, widely held financial institutions, families, the state,and dispersed shareholders according to data available from Claessens et al.[2000] and Faccio and Lang [2002]. Most relevant to our purposes, CON-NECTED remains positive and statistically significant at the 5% level in bothregressions, reinforcing our earlier evidence on the link between politicalconnection and auditor choice.
4.1.2.3. Alternative Dependent Variables. There are reasons to doubt thatBIG 4 is the relevant construct for all of the countries represented in our
litigation costs in the event of audit failure, this evidence is sensitive to shifts in the auditorlitigation liability landscape there (e.g., Jones and Raghunandan [1998], Francis and Reynolds[2003], Choi, Doogar, and Ganguly [2004]).
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 131
sample. For example, although table 2 reports that the Big 4 audit nearly82% of the politically connected firms in our sample, data inspection re-veals wide variation in their market shares across countries. Consequently,we respecify auditor choice by coding a dummy variable, LARGEST FIVE,one when the auditor is among the five largest in the country accordingto client assets, and zero otherwise. In unreported analysis, we find thatCONNECTED remains positive and statistically significant at the 5% levelwhen we replace BIG 4 with this alternate dependent variable. We find al-most identical evidence when we calibrate market share with the numberof clients rather than their assets (e.g., Wang, Wong, and Xia [2008]), oridentify large auditors as those that hold at least a 5% market share in thecountry (e.g., DeFond, Wong, and Li [2000]).17
4.2 POLITICAL CONNECTIONS AND AUDITOR CHOICE: THE MEDIATINGROLE OF FIRMS’ OWNERSHIP STRUCTURES
In table 5, we examine in panel A whether the importance of politi-cal connections to auditor choice varies systematically with the extent ofagency costs embedded in firms’ ownership structures. Initially, we estimatewhether the relation between auditor choice and political ties is sensitiveto the presence of any wedge between the controlling shareholder’s vot-ing rights and cash flow rights. To ensure that we draw valid inferencesconcerning the interaction, we also report the corrected mean interac-tive effect of the interaction terms using the methodology proposed byAi and Norton [2003] for nonlinear models. In model 1, we find that theOWNERSHIPWEDGE∗CONNECTED interaction has no perceptible impacton auditor choice, inconsistent with the prediction in H2 that control di-verging from ownership explains demand for high-quality auditors in con-nected firms. Next, we analyze in model 2 whether connected firms aremore likely to hire a Big 4 auditor when the control rights of the ultimateowner exceed 50% and find supportive results.
Consistent with the prediction in H2, we find evidence in model 3 thatconnected firms with a single large shareholder are more likely to appoint aBig 4 auditor, implying that they rely more heavily on external monitoringby high-quality auditors in the absence of internal monitoring by multi-ple large shareholders. This evidence persists in model 4 when we replacethe dummy variable representing the absence of multiple major sharehold-ers with a continuous version of this conditioning variable, NUMBER OF
17 Another issue is that the Big 4 are prohibited from operating in some countries unlessthey form affiliations with local auditors. It follows that audit quality falls when the country re-quires the Big 4 to arrange these local affiliations to access the market. After identifying thesecases using Worldscope data, we narrow our BIG 4 specification to strictly firms from coun-tries that do not require local affiliations; that is, we treat Big 4 auditors with local affiliationsas equivalent to non–Big 4 auditors. In this re-specification, we continue to find evidence atthe 5% level supporting the prediction in H1 that connected firms are more likely to preferhigher-quality auditors.
132 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
TA
BL
E5
Polit
ical
Con
nect
ions
and
Aud
itor
Cho
ice
Pan
elA
:The
med
iati
ngro
leof
the
owne
rshi
pst
ruct
ure
OW
NER
SHIP
CO
NT
RO
LSI
NG
LE
NU
MB
ERO
FB
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NES
SW
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ER
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TS
>50
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GE
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NER
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RO
UP
Mod
els
12
34
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WN
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ED0.
13(0
.29)
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NT
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TS
>50
×C
ON
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TED
1.12
∗
(1.8
8)SI
NG
LEL
AR
GEO
WN
×C
ON
NEC
TED
1.25
∗∗
(2.2
5)N
UM
BER
OF
LA
RG
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WN
ERS
×C
ON
NEC
TED
−0.8
4∗∗
(−2.
02)
BU
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×C
ON
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TED
1.76
∗∗∗
(2.8
8)In
terc
ept
−2.9
2∗∗−2
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−2.3
7∗∗−3
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6∗
(−2.
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07)
(−1.
96)
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44)
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[Mar
gin
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[14.
59]
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[14.
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#VA
RIA
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ES×
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%]
Mea
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−0.1
2∗0.
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#VA
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(−1.
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(1.7
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R2
0.09
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0.11
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χ2
91.8
494
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106.
810
6.8
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0N
2,69
02,
690
2,44
32,
443
2,62
5
(Con
tinue
d)
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 133
TA
BL
E5—
Con
tinue
d
Pan
elB
:The
med
iati
ngro
leof
the
firm
char
acte
rist
ics
NEG
-B
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KR
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(−2.
28)
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∗∗
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6)X
DO
PS×
CO
NN
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(2.1
6)B
AN
KR
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ITY
×C
ON
NEC
TED
0.02
∗
(1.8
6)C
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NN
ECT
ED0.
35∗∗
∗
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9)C
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×C
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TED
0.62
(0.6
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EVER
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48)
FIN
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(−0.
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Inte
rcep
t−2
.72∗∗
−2.7
6∗∗−2
.56∗∗
−2.7
1∗∗−3
.15∗∗
−2.7
3∗∗−2
.78∗∗
−2.8
8∗∗−2
.81∗∗
(−2.
31)
(−2.
38)
(−2.
22)
(−2.
35)
(−2.
54)
(−2.
35)
(−2.
41)
(−2.
49)
(−2.
44)
[Mar
gin
alef
fect
of[2
.07]
[−13
.99]
[1.3
3][9
.81]
[0.3
3][5
.26]
[7.7
3][−
0.18
][−
2.71
]#V
AR
IAB
LES
×C
ON
NEC
TED
in%
]M
ean
inte
ract
ive
effe
ctof
0.01
−0.1
1∗0.
01∗
0.10
∗0.
000.
05∗∗
0.01
−0.0
01−0
.03
#VA
RIA
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ES×
CO
NN
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ED(0
.96)
(−1.
90)
(1.8
5)(1
.80)
(1.6
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.22)
(0.0
6)(−
1.20
)(−
0.39
)Ps
eudo
R2
0.09
0.09
0.09
0.09
0.10
0.09
0.09
0.09
0.09
χ2
93.0
693
.06
96.6
692
.42
89.6
493
.57
90.9
491
.88
90.3
6N
2,69
02,
690
2,69
02,
690
2,39
52,
690
2,69
02,
690
2,69
0
(Con
tinue
d)
134 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFART
AB
LE
5—C
ontin
ued
Pan
elC
:The
med
iati
ngro
leof
the
coun
try-
leve
lvar
iabl
esN
EWSP
APE
RPO
LIT
ICA
LO
PPEL
ECT
ION
BA
NK
DEP
FIN
SYSD
EP
Mod
els
12
34
5N
EWSP
APE
R×
CO
NN
ECT
ED0.
02(0
.07)
POL
ITIC
AL
OPP
×C
ON
NEC
TED
2.27
∗
(1.8
2)EL
ECT
ION
×C
ON
NEC
TED
0.53
∗
(1.9
3)B
AN
KD
EP×
CO
NN
ECT
ED−0
.01∗
(−1.
82)
FIN
SYSD
EP×
CO
NN
ECT
ED−0
.01∗
(−1.
86)
Inte
rcep
t−1
.71
−2.3
9∗∗−2
.78∗∗
−1.0
1−0
.99
(−1.
46)
(−2.
05)
(−2.
41)
(−0.
78)
(−0.
76)
[Mar
gin
alef
fect
of#V
AR
IAB
LES
×C
ON
NEC
TED
in%
][0
.25]
[35.
20]
[6.8
6][0
.13]
[0.1
3]M
ean
inte
ract
ive
effe
ctof
#VA
RIA
BL
ES×
CO
NN
ECT
ED−0
.05
0.23
0.06
∗−0
.001
∗−0
.001
∗
(−1.
58)
(1.0
5)(1
.77)
(−1.
75)
(−1.
78)
Pseu
doR
20.
110.
090.
090.
100.
10χ
210
9.7
97.2
294
.48
83.3
583
.86
N2,
544
2,54
42,
690
1,98
81,
988
Th
ista
ble
repo
rts
resu
lts
onth
ero
leof
own
ersh
ipch
arac
teri
stic
s(p
anel
A),
oth
erfi
rmch
arac
teri
stic
s(p
anel
B),
and
coun
try-
leve
lvar
iabl
es(p
anel
C)
inco
ndi
tion
ing
the
impa
ctof
polit
ical
con
nec
tion
son
audi
tor
choi
ce.I
nal
lspe
cifi
cati
ons,
we
use
mod
el3
inta
ble
3as
the
base
line
regr
essi
on.I
npa
nel
A,t
he
own
ersh
ipva
riab
les
inte
ract
edw
ith
CO
NN
ECT
EDar
eth
ew
edge
betw
een
the
con
trol
ling
shar
ehol
der’
svo
tin
gri
ghts
and
cash
flow
righ
ts(O
WN
ERSH
IPW
EDG
E)in
mod
el1,
adu
mm
yva
riab
lefo
rw
het
her
con
trol
righ
tsof
the
ulti
mat
eow
ner
exce
ed50
%(C
ON
TR
OL
RIG
HT
S>50
)in
mod
el2,
the
pres
ence
ofa
sin
gle
larg
esh
areh
olde
r(S
ING
LEL
AR
GEO
WN
)in
mod
el3,
the
num
ber
ofm
ulti
ple
maj
orsh
areh
olde
rs(N
UM
BER
OF
LA
RG
EO
WN
ERS)
inm
odel
4,an
da
dum
my
vari
able
indi
cati
ng
busi
nes
sgr
oup
affi
liati
on(B
USI
NES
SGR
OU
P)in
mod
el5.
Inpa
nel
B,t
he
firm
char
acte
rist
ics
inte
ract
edw
ith
CO
NN
ECT
EDar
efi
rmsi
ze(S
IZE)
inm
odel
1,a
dum
my
vari
able
for
loss
firm
s(N
EGEA
RN
ING
S)in
mod
el2,
capi
tal
expe
ndi
ture
s(C
APE
X)
inm
odel
3,a
dum
my
vari
able
for
firm
sre
port
ing
extr
aord
inar
yit
ems
ordi
scon
tin
ued
oper
atio
ns
(XD
OPS
)in
mod
el4,
the
chan
gein
ban
krup
tcy
prob
abili
ty(B
AN
KR
UPT
CY
PRO
BA
BIL
ITY)
inm
odel
5,cu
rren
tas
sets
rati
o(C
UR
REN
TA
SSET
S)in
mod
el6,
cros
s-lis
tin
gst
atus
(CR
OSS
-LIS
TIN
G)
inm
odel
7,le
vera
ge(L
EVER
AG
E)in
mod
el8,
and
fin
anci
ng
dem
and
(FIN
AN
CIN
G)
inm
odel
9.In
pan
elC
,th
eco
untr
y-le
velv
aria
bles
inte
ract
edw
ith
CO
NN
ECT
EDar
eth
eci
rcul
atio
nof
daily
new
spap
ers
divi
ded
bypo
pula
tion
(NEW
SPA
PER
)in
mod
el1,
the
stre
ngt
hof
polit
ical
oppo
siti
on(P
OL
ITIC
AL
OPP
)in
mod
el2,
adu
mm
yva
riab
lein
dica
tin
gw
het
her
itis
an
atio
nal
elec
tion
year
(EL
ECT
ION
)in
mod
el3,
and
the
tota
lval
ueof
ban
k(fi
nan
cial
syst
em)
depo
sits
toG
DP
inm
odel
4(m
odel
5).B
enea
thea
ches
tim
ate
isre
port
edth
ero
bust
z-st
atis
tic
clus
tere
dat
both
the
coun
try
and
the
firm
leve
l.T
he
tabl
eal
sore
port
sth
em
argi
nal
effe
ctof
each
inte
ract
ion
term
and
the
mea
nin
tera
ctiv
eef
fect
usin
gth
em
eth
odol
ogy
prop
osed
byA
ian
dN
orto
n[2
003]
.∗∗∗ ,
∗∗,a
nd
∗de
not
est
atis
tica
lsig
nifi
can
ceat
the
1%,5
%,
and
10%
leve
ls,r
espe
ctiv
ely,
base
don
two-
side
dte
sts.
Th
ede
fin
itio
ns
and
data
sour
ces
for
the
vari
able
sar
eou
tlin
edin
tabl
eA
1.R
esul
tsfo
rth
eco
ntr
olva
riab
les
are
not
repo
rted
for
the
sake
ofbr
evit
y.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 135
LARGE OWNERS, which is the natural logarithm of one plus the numberof shareholders holding at least a 10% equity stake. These results reinforcethat committed monitoring by several large shareholders obviates the disci-plinary role that Big 4 audits play in connected firms.
Similarly, the interaction between BUSINESSGROUP and CONNECTEDloads positively in model 5, implying that Big 4 appointments become morelikely when connected firms belong to a business group. We also estimatea positive and significant mean interactive effect (reported at the bottomof model 5). Our results square with Faccio’s [2006] evidence that cumu-lative abnormal returns surrounding politicians joining firms’ boards arenegative when the connected firm has a pyramidal ownership structurethat increases agency costs since expropriation becomes more lucrative forthe controlling shareholder as the gap between their voting and cash flowrights widens (e.g., Johnson et al. [2000], La Porta et al. [2002], Fan andWong [2005]).
Collectively, the evidence in panel A of table 5 generally supports the in-tuition that connected firms are even more eager to engage high-qualityauditors when their ownership structures leave minority investors morevulnerable to expropriation by dominant shareholders. Economically, ourcoefficient estimates translate into connected firms (i) with the ultimateowner’s control rights exceeding 50%; (ii) with a single large shareholder;and (iii) affiliated with a business group becoming 12%, 15%, and 15%more likely to appoint a Big 4 auditor, respectively, with the rest of the re-gression variables set to their mean values.
In panel B of table 5, we complement the cross-sectional results involv-ing ownership structure by analyzing whether the link between politicalconnections and auditor choice hinges on other firm-level characteristics.More specifically, we follow prior research by examining the role that clientsize, profitability, complexity, financial constraints, and risk play in shapingconnected firms’ demand for Big 4 auditors (e.g., Fan and Wong [2005],Hay, Knechel, and Wong [2006], Chang, Dasgupta, and Hilary [2009],Sankaraguruswamy, Whisenant, and Willenborg [2013]). Consistent withexpectations, we report in models 1–6 evidence that connected firms thatare larger have positive earnings in the past year, have larger capital ex-penditures, are more complex according to the presence of extraordinaryitems or discontinued operations, exhibit a greater change in bankruptcyprobability, and have more current assets—firms with higher levels of inven-tory and receivables are harder to audit—are more likely to rely on a Big 4auditor.18 Except for models 1 and 5, the mean interactive effects reported
18 We continue to find supportive evidence when we replace the dummy variable forwhether the firm has incurred a loss in a prior year with its return on equity to capture prof-itability. Similarly, our results in table 5 are robust to measuring client size with revenues ratherthan assets. We resort to alternative proxies for some constructs when poor data availabilitymeans that we cannot examine more standard measures. For example, we follow Whisenant,Sankaraguruswamy, and Raghunandan [2003] and Sankaraguruswamy, Whisenant, and
136 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
at the bottom of panel B are statistically significant. In contrast, we find noevidence in model 7 supporting that connected firms that are cross-listedtend to prefer higher-quality auditors. Similarly, in untabulated results thatshift the focus from foreign financing to foreign operations, this interac-tion remains statistically insignificant when we replace cross-listing with theamount of foreign sales to gauge firms’ international orientation. In mod-els 8 and 9, we also fail to find that connected firms with more debt in theircapital structures or requiring more external financing exhibit greater de-mand for Big 4 auditors; both LEVERAGE and FINANCING are irrelevant toauditor choice according to table 3.
In the first three regressions in panel C of table 5, we examine therole of public scrutiny in shaping auditor choice in politically connectedfirms. This analysis is rooted in the intuition that connections increasethe exposure of insiders to public scrutiny from the press and politicalopponents, reducing their ability and incentives to extract private bene-fits (Stulz [2005]). In short, subjecting connected firms to tough publicscrutiny constrains their diversionary instincts. Consequently, these firmswill prefer to appoint Big 4 auditors since they have nothing to hide whenthey refrain from self-dealing. In successive regressions, we interact CON-NECTED with three variables reflecting the extent of media and politicaloversight, namely the circulation of daily newspapers divided by popula-tion (NEWSPAPER) from Dyck and Zingales [2004], the strength of polit-ical opposition (POLITICALOPP) obtained from the Database of PoliticalInstitutions (Beck et al. [2001]), and a dummy variable indicating whetherit is a national election year (ELECTION) from the Database of PoliticalInstitutions. The results generally indicate that these variables conditionthe link between political connections and auditor choice in the predicteddirections. More specifically, the interaction terms between CONNECTEDand the variables measuring the strength of political opposition (model 2)and the presence of an election year (model 3) load positively, althoughwe fail to find supportive results when we focus on the role of the press inmodel 1. The positive mean interactive effects reported in models 2 and 3reinforce our conclusions. Next, we evaluate whether the countries’ debtmarket development mediates the link between political ties and auditorchoice given Chaney, Faccio, and Parsley’s [2011] evidence on the impor-tance of political connections to firms’ borrowing costs. We measure debtmarket development with the total value of bank (financial system) depositsto GDP in model 4 (model 5). In both regressions, we find evidence imply-ing that connected firms in countries with more developed debt markets
Willenborg [2013] in gauging firm complexity with the presence of extraordinary items ordiscontinued operations, rather than the number of subsidiaries, the audit report lag, orthe presence of pension or other postretirement plans. However, the interaction with CON-NECTED becomes statistically insignificant when we measure client complexity with the num-ber of business segments.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 137
are less likely to hire Big 4 auditors; the mean interactive effects are alsonegative and statistically significant.
4.3 DOES COUNTRY-LEVEL GOVERNANCE AFFECT THE LINK BETWEENPOLITICAL CONNECTION AND AUDITOR CHOICE?
Given prior research that the value of political connections is higherin weaker institutional environments, it follows that insiders resisting thetemptation to expropriate outside investors will have even more incentiveto improve external monitoring by hiring a Big 4 auditor in these countries.Consequently, we examine the prediction in H3 that the relation betweenpolitical connections and auditor choice is stronger in countries with rela-tively lax governance institutions by re-estimating the regression in model 3in table 3 after bisecting the sample into countries with weak versus stronggovernance according to the median rating of the various proxies describedin section 3.2.19
Table 6 presents the results after dividing the sample using the four prox-ies for country-level governance, RESTRICTIONS, EXPROPRIATION, ANTI-SELF, and PROTECTION. We find across all proxies that the coefficienton CONNECTED is positive and statistically significant in the subsample offirms located in countries with weak governance institutions (models 1, 3, 5,and 7), suggesting that political connections magnify the demand for high-quality audits in these situations.20 However, in stark contrast, we find thatthe coefficient on CONNECTED is statistically indistinguishable from zeroin the subsample of countries with strong governance institutions (models2, 4, 6, and 8). The difference in the CONNECTED coefficients between thesamples of weak and strong institutional environments is statistically signif-icant for two out of the four country-level governance variables; the excep-tions are the comparisons involving RESTRICTIONS and EXPROPRIATION.In unreported regressions, we control for the largest shareholder’s equitystake (LARGEOWN) rather than their control rights (CONTROLRIGHTS) inorder to recover observations by improving the country coverage in table 6to 28 from 19, and find that the CONNECTED coefficients are significantlydifferent between the countries with weak and strong governance institu-tions in all four comparisons. These results lend support to the intuition
19 This split sample design with respect to country-level variables follows extensive prior re-search (e.g., Lang, Lins, and Miller [2004], Pinkowitz, Stulz, and Williamson [2006], Wang[2010]). In an important advantage, this approach avoids multicollinearity complications aris-ing from the high correlations between the test variables and their interaction terms, especiallywhen the interaction involves a dummy variable and country-level time invariant variables. In-deed, in our analysis, the Belsley collinearity test indicates a score above the threshold of 30when we include the interaction terms.
20 Economically, our evidence in this section implies that the importance of political con-nections to auditor choice is generally larger when we isolate firms from countries with rela-tively poor governance institutions. For the full sample, the regression in model 3 in table 3suggests that the probability of hiring a Big 4 auditor rises 8% in the presence of a politicalconnection. In comparison, the coefficient estimates for CONNECTED translate into an 8%impact in model 1 in table 6, 9% in model 3, 13% in model 5, and 14% in model 7.
138 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFART
AB
LE
6Po
litic
alC
onne
ctio
nsan
dA
udito
rC
hoic
e:T
heM
edia
ting
Rol
eof
Cou
ntry
-Lev
elIn
stitu
tions
RES
TR
ICT
ION
SR
EST
RIC
TIO
NS
EXPR
OPR
IAT
ION
EXPR
OPR
IAT
ION
AN
TIS
ELF
AN
TIS
ELF
PRO
TEC
TIO
NPR
OT
ECT
ION
Vari
able
Low
Hig
hH
igh
Low
Low
Hig
hL
owH
igh
Mod
els
12
34
56
78
CO
NN
ECT
ED0.
60∗
0.42
0.71
∗∗0.
180.
87∗∗
−0.1
10.
97∗∗
∗−0
.23
(1.8
0)(1
.35)
(2.0
8)(0
.63)
(2.5
3)(−
0.37
)(2
.85)
(−0.
71)
CO
NT
RO
LR
IGH
TS
2.70
∗−2
.00∗∗
∗−1
.37∗∗
0.59
−0.8
1−1
.19∗
−1.6
4∗∗−1
.32∗
(1.7
3)(−
3.66
)(−
2.32
)(0
.54)
(−0.
95)
(−1.
67)
(−2.
05)
(−1.
78)
CO
MPL
EXIT
Y0.
15−0
.08
−0.1
00.
050.
050.
040.
050.
01(1
.28)
(−0.
78)
(−1.
01)
(0.3
6)(0
.50)
(0.2
7)(0
.47)
(0.1
0)FO
REI
GN
SAL
ES0.
010.
01∗∗
0.01
0.01
∗∗0.
010.
01−0
.00
0.01
(1.4
7)(1
.99)
(1.5
4)(2
.11)
(1.1
8)(1
.64)
(−0.
06)
(1.6
3)FI
NA
NC
ING
−0.2
20.
390.
64−0
.25
0.32
0.39
0.27
0.36
(−0.
48)
(0.9
9)(1
.47)
(−0.
62)
(0.7
0)(1
.03)
(0.6
3)(0
.97)
CR
OSS
-LIS
TIN
G1.
09∗
0.39
0.81
∗1.
110.
680.
560.
550.
69(1
.73)
(0.8
4)(1
.79)
(1.2
6)(1
.54)
(0.4
9)(1
.10)
(0.5
9)SI
ZE0.
080.
22∗∗
∗0.
14∗
0.05
0.10
∗∗0.
44∗∗
∗0.
16∗∗
∗0.
48∗∗
∗
(1.4
7)(3
.32)
(1.9
4)(1
.13)
(2.1
4)(5
.22)
(3.0
3)(5
.47)
STAT
EOW
N−0
.01
0.03
0.03
−0.0
6−0
.13∗
0.01
−0.1
6∗∗∗
0.00
(−0.
12)
(0.4
9)(0
.55)
(−0.
79)
(−1.
90)
(0.1
0)(−
2.66
)(0
.05)
RO
A3.
20∗∗
1.76
∗∗2.
20∗∗
∗2.
36∗
1.20
2.63
∗∗∗
1.13
2.41
∗∗∗
(2.5
1)(2
.07)
(2.6
9)(1
.82)
(0.9
3)(2
.83)
(0.8
0)(2
.70)
LEV
ERA
GE
0.10
−0.1
70.
28∗
−0.1
20.
20−0
.27
0.19
−0.3
5(0
.50)
(−0.
90)
(1.6
7)(−
0.59
)(1
.24)
(−1.
17)
(1.2
3)(−
1.57
)G
RO
WT
H0.
00−0
.00
−0.0
10.
00−0
.00
−0.0
1−0
.00
−0.0
1(0
.16)
(−0.
66)
(−1.
25)
(0.4
6)(−
0.20
)(−
1.14
)(−
0.25
)(−
1.35
)IN
V−0
.36
−2.1
0∗−1
.88∗
−0.6
7−1
.32
−0.2
7−1
.10
−0.4
3(−
0.27
)(−
1.94
)(−
1.70
)(−
0.52
)(−
1.06
)(−
0.21
)(−
0.82
)(−
0.34
)FD
I−0
.07∗∗
0.04
0.01
−0.0
4−0
.08∗∗
−0.0
0−0
.05∗
−0.0
0(−
2.28
)(1
.17)
(0.2
8)(−
1.46
)(−
2.52
)(−
0.11
)(−
1.81
)(−
0.04
)
(Con
tinue
d)
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 139
TA
BL
E6—
Con
tinue
d
RES
TR
ICT
ION
SR
EST
RIC
TIO
NS
EXPR
OPR
IAT
ION
EXPR
OPR
IAT
ION
AN
TIS
ELF
AN
TIS
ELF
PRO
TEC
TIO
NPR
OT
ECT
ION
Vari
able
Low
Hig
hH
igh
Low
Low
Hig
hL
owH
igh
LG
DPC
0.52
∗∗∗
−0.0
9−0
.39
0.29
∗∗0.
29∗∗
0.73
∗∗∗
0.22
∗0.
73∗∗
∗
(3.5
1)(−
0.40
)(−
0.31
)(2
.01)
(2.5
6)(2
.96)
(1.8
4)(2
.90)
SUE
AU
DIT
OR
0.22
2.12
∗∗∗
3.76
∗∗∗
−0.4
52.
82∗∗
∗−1
.06
0.04
1.57
(0.0
7)(3
.23)
(3.6
3)(−
0.74
)(3
.31)
(−0.
87)
(0.0
6)(0
.51)
Inte
rcep
t−6
.30∗
−1.3
61.
36−2
.13
−5.2
3∗∗∗
−10.
15∗∗
∗−3
.82∗∗
−12.
28∗∗
∗
(−1.
87)
(−0.
53)
(0.1
2)(−
1.23
)(−
2.90
)(−
3.72
)(−
2.09
)(−
2.86
)[M
argi
nal
effe
ctof
CO
NN
ECT
EDin
%]
[8.0
2][5
.72]
[8.9
3][2
.78]
[12.
93]
[−1.
17]
[14.
33]
[−2.
36]
p-va
lue
for
diff
eren
cein
CO
NN
ECT
EDco
effi
cien
t
[0.6
9][0
.23]
[0.0
3]∗∗
[0.0
1]∗∗
∗
Pseu
doR
20.
090.
160.
170.
060.
140.
160.
120.
17χ
254
.62
75.7
288
.76
31.7
276
.48
72.1
770
.53
74.3
9N
1,18
71,
503
1,65
11,
039
1,42
61,
264
1,44
31,
247
For
subs
ampl
esof
wea
kve
rsus
stro
ng
gove
rnan
ceco
untr
ies,
this
tabl
ere
port
spo
oled
logi
test
imat
ion
resu
lts
for
audi
tor
choi
cefo
rpo
litic
ally
con
nec
ted
firm
san
dn
onco
nn
ecte
dpe
ers
usin
gm
odel
3in
tabl
e3
asth
eba
selin
ere
gres
sion
.Mod
els
1an
d2
repo
rtth
ere
sult
sfo
rsu
bsam
ples
offi
rms
from
coun
trie
sw
ith
low
and
hig
hre
gula
tory
scor
es(R
EST
RIC
-T
ION
S),r
espe
ctiv
ely.
Mod
els
3an
d4
repo
rtth
ere
sult
sfo
rsu
bsam
ples
offi
rms
from
coun
trie
sw
ith
hig
han
dlo
wri
skof
expr
opri
atio
n(E
XPR
OPR
IAT
ION
),re
spec
tive
ly.M
odel
s5
and
6re
port
the
resu
lts
for
subs
ampl
esof
firm
sfr
omco
untr
ies
wit
hlo
wan
dh
igh
scor
eson
the
anti
-sel
f-dea
ling
inde
x(A
NT
ISEL
F),r
espe
ctiv
ely.
Mod
els
7an
d8
repo
rtth
ere
sult
sfo
rsu
bsam
ples
offi
rms
from
coun
trie
sw
ith
low
and
hig
hin
vest
orpr
otec
tion
scor
es(P
RO
TEC
TIO
N),
resp
ecti
vely
.Ben
eath
each
esti
mat
eis
repo
rted
the
robu
stz-
stat
isti
ccl
uste
red
atbo
thth
eco
untr
yan
dth
efi
rmle
vel.
Th
eta
ble
also
repo
rts
the
mar
gin
alef
fect
ofth
eva
riab
leC
ON
NEC
TED
and
the
p-va
lue
for
the
diff
eren
cein
the
CO
NN
ECT
EDco
effi
cien
tbet
wee
nth
ew
eak
and
stro
ng
inst
itut
ion
subs
ampl
es.
Th
est
anda
rder
rors
for
the
diff
eren
ces
betw
een
wea
kan
dst
ron
gin
stit
utio
ns
regr
essi
ons
are
com
pute
dw
ith
ase
emin
gly
unre
late
dre
gres
sion
(SU
R)
syst
emth
ates
tim
ates
both
grou
psjo
intl
y.∗∗
∗ ,∗∗
,an
d∗
den
ote
stat
isti
cal
sign
ifica
nce
atth
e1%
,5%
,an
d10
%le
vels
,res
pect
ivel
y,ba
sed
ontw
o-si
ded
test
s.T
he
defi
nit
ion
san
dda
taso
urce
sfo
rth
eva
riab
les
are
outl
ined
inta
ble
A1.
140 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
that the incentives of politically connected firms to appoint a Big 4 auditorare stronger in countries with relatively poor governance institutions.
4.4 ECONOMIC OUTCOMES STEMMING FROM AUDITOR CHOICEIN POLITICALLY CONNECTED FIRMS
The analysis above suggests that politically connected firms are morelikely to engage a Big 4 auditor, especially when they suffer more severeagency problems and operate in countries with relatively lax country-levelgovernance institutions. This evidence naturally raises another question:why are these firms more eager to engage a Big 4 auditor? Extant researchdetects that firms with better auditors enjoy higher-quality earnings (e.g.,Becker et al. [1998]), higher valuations (e.g., Fan and Wong [2005]), andlower cost of capital (e.g., Mansi, Maxwell, and Miller [2004]). However,there is evidence that connected firms have preferential access to credit(e.g., Khwaja and Mian [2005]) and are more likely to be bailed out by gov-ernments (Faccio, Masulis, and McConnell [2006]). In other words, someresearch implies that the upside of tough external monitoring by Big 4auditors may be minimal for connected firms. In the other direction, thepresence of a Big 4 auditor protects outside investors by constraining in-siders’ discretion over the financial reporting process, which may translateinto connected firms benefiting from lower information asymmetry. In thissection, we contribute to empirically settling this issue by testing the predic-tion in H4 that politically connected firms appointing a Big 4 auditor prac-tice less earnings management, enjoy greater transparency, exhibit highervaluations, and attract cheaper financing.
In table 7, we report the results of this analysis, which involves interactingauditor choice with the variable CONNECTED to isolate whether politicallyconnected firms benefit more from becoming better known by hiring a Big4 auditor. In focusing on the interaction term between CONNECTED andauditor choice, we examine an extensive set of firm-level outcome variablesmotivated by prior research, namely earnings management (e.g., Beckeret al. [1998], Chaney, Faccio, and Parsley [2011]); analyst forecast coverageand accuracy (e.g., Lang, Lins, and Miller [2004], Lang, Lins, and Maffett[2012], Chen, Ding, Kim [2010]); accounting standard choice (e.g., Langand Maffett [2011], Lang, Lins, and Maffett [2012]); valuation (e.g., Fanand Wong [2005]); and equity pricing (e.g., Khurana and Raman [2004]).
We initially examine the impact of auditor choice on earnings manage-ment since providing evidence that the presence of a Big 4 auditor reducesinformation asymmetry evident in accounting transparency is arguably anecessary condition for proceeding to analyze, for example, whether Big 4clients enjoy higher valuations and lower equity financing costs. After Fanand Wong [2005], we implement a two-stage estimation procedure. In thefirst stage, we predict, for each firm-year, the probability of choosing a Big4 auditor using model 1 in table 3. In the second stage, we regress earningsmanagement (EM)—specified after Leuz, Nanda, and Wysocki [2003] asthe absolute value of accruals over total assets where accruals are calculated
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 141
TA
BL
E7
Ana
lysi
sof
the
Impo
rtan
ceof
Aud
itor
Cho
ice
toEa
rnin
gsM
anag
emen
t,Tr
ansp
aren
cy,M
arke
tVal
uatio
n,an
dEq
uity
Pric
ing
(1)
Ear
nin
gsM
anag
emen
t(EM
)(2
)A
nal
ystF
ollo
win
g(A
NA
LYST
S)(3
)Fo
reca
stA
ccur
acy
(AC
CU
RA
CY)
Vari
able
Vari
able
Vari
able
PBIG
4∗C
ON
NEC
TED
−0.1
2∗∗∗
PBIG
4∗C
ON
NEC
TED
1.62
∗∗PB
IG4∗
CO
NN
ECT
ED0.
13∗∗
∗
(−2.
67)
(2.4
4)(3
.06)
PBIG
40.
05PB
IG4
1.04
PBIG
40.
01(1
.45)
(1.4
5)(0
.37)
CO
NN
ECT
ED0.
09∗∗
∗C
ON
NEC
TED
−1.4
2∗∗C
ON
NEC
TED
−0.1
1∗∗∗
(2.7
4)(−
2.52
)(−
2.98
)R
OA
−0.1
0∗∗∗
CR
OSS
-LIS
TIN
G0.
13C
RO
SS-L
IST
ING
−0.0
0(−
4.14
)(1
.37)
(−0.
85)
SIZE
−0.0
0SI
ZE0.
27∗∗
∗SI
ZE−0
.00∗
(−1.
46)
(10.
20)
(−1.
74)
GR
OW
TH
−0.0
0L
AR
GEO
WN
−0.0
4A
NA
LYST
S0.
00(−
0.81
)(−
0.20
)(1
.20)
LEV
ERA
GE
0.01
STAT
EOW
N0.
02N
EGEA
RN
ING
S0.
08∗∗
(1.3
4)(1
.59)
(2.3
4)L
AR
GEO
WN
0.01
GR
OW
TH
0.00
CH
AN
GE
EAR
NIN
GS
−0.0
0(0
.57)
(1.3
2)(−
0.66
)C
RO
SS-L
IST
ING
−0.0
0VA
RIA
NC
E0.
23C
IFA
R−0
.00
(−0.
43)
(1.3
6)(−
0.96
)ST
ATEO
WN
−0.0
0EA
RN
ING
SSU
RPR
ISE
−1.6
9∗A
NT
ISEL
F−0
.00
(−0.
36)
(−1.
82)
(−0.
17)
LAW
OR
DER
0.00
Inte
rcep
t−3
.20∗∗
∗EA
RN
ING
SM
GN
−0.0
0(0
.17)
(−5.
88)
(−0.
64)
SEC
REG
−0.0
0L
IST
EDFI
RM
S0.
00(−
0.34
)(0
.31)
AN
TIS
ELF
−0.0
5∗∗∗
IDV
−0.0
0(−
2.96
)(−
0.41
)
(Con
tinue
d)
142 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
TA
BL
E7—
Con
tinue
d
(1)
Ear
nin
gsM
anag
emen
t(EM
)(2
)A
nal
ystF
ollo
win
g(A
NA
LYST
S)(3
)Fo
reca
stA
ccur
acy
(AC
CU
RA
CY)
Vari
able
Vari
able
Vari
able
STO
CK
TR
AD
−0.0
0U
AI
0.00
(−0.
42)
(1.0
5)In
terc
ept
0.14
∗∗∗
Inte
rcep
t0.
04(5
.10)
(0.9
0)A
djus
ted
R2
0.09
Adj
uste
dR
20.
53A
djus
ted
R2
0.09
N1,
661
N1,
126
N84
2
(4)
Acc
oun
tin
gSt
anda
rdC
hoi
ce(I
AS)
(5)
Mar
ketV
alua
tion
(MT
B)
(6)
Cos
tofE
quit
y(K
MED
)
Vari
able
Vari
able
Vari
able
PBIG
4×
CO
NN
ECT
ED5.
10∗∗
PBIG
4∗C
ON
NEC
TED
1.38
∗∗PB
IG4∗
CO
NN
ECT
ED−5
.97∗∗
∗
(2.4
0)(2
.23)
(−2.
73)
PBIG
40.
39PB
IG4
0.72
∗∗PB
IG4
3.15
∗
(0.2
2)(2
.26)
(1.8
3)C
ON
NEC
TED
−4.0
1∗∗C
ON
NEC
TED
−1.0
1∗∗C
ON
NEC
TED
4.77
∗∗∗
(−2.
25)
(−2.
05)
(2.5
9)L
AR
GEO
WN
0.53
SIZE
−0.0
3∗∗SI
ZE−0
.32∗∗
∗
(1.2
0)(−
2.14
)(−
6.41
)FO
REI
GN
SAL
ES0.
00G
RO
WT
H0.
02∗∗
∗VA
RIA
NC
E7.
33∗∗
∗
(1.1
4)(9
.00)
(10.
24)
CF
−0.0
0L
AR
GEO
WN
−0.1
9FB
IAIS
9.32
∗∗
(−0.
50)
(−1.
16)
(2.3
7)FI
NA
NC
ING
−0.0
5C
RO
SS-L
IST
ING
0.13
MT
B−0
.39∗∗
∗
(−0.
19)
(0.8
7)(−
8.37
)C
RO
SS-L
IST
ING
0.15
FOR
EIG
NSA
LES
0.00
∗∗D
ISC
LO
SE−1
.49∗
(0.4
5)(2
.22)
(−1.
82)
SIZE
−0.2
5∗∗∗
CA
PEX
−0.0
0M
AC
VAR
8.55
∗∗∗
(−4.
01)
(−0.
50)
(4.4
0)
(Con
tinue
d)
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 143
TA
BL
E7—
Con
tinue
d
(4)
Acc
oun
tin
gSt
anda
rdC
hoi
ce(I
AS)
(5)
Mar
ketV
alua
tion
(MT
B)
(6)
Cos
tofE
quit
y(K
MED
)
Vari
able
Vari
able
Vari
able
LEV
ERA
GE
0.48
∗∗∗
AN
TIS
ELF
−0.1
2L
AWO
RD
ER−0
.22∗
(3.9
8)(−
0.70
)(−
1.69
)T
UR
NO
VER
−0.2
6∗In
terc
ept
2.08
∗∗∗
INFL
ATIO
N0.
45∗∗
∗
(−1.
82)
(5.8
8)(2
.97)
GR
OW
TH
0.01
∗In
terc
ept
11.5
4∗∗∗
(1.7
2)(4
.77)
LG
DPC
0.26
∗
(1.8
1)A
NT
ISEL
F−4
.50∗∗
∗
(−7.
71)
STO
CK
TR
AD
0.21
(0.8
2)C
IFA
R0.
07∗∗
∗
(3.4
7)In
terc
ept
−16.
46∗∗
∗
(−6.
87)
[Mar
gin
alef
fect
ofPB
IG4
×C
ON
NEC
TED
in%
][4
4.71
]
Mea
nin
tera
ctiv
eef
fect
of0.
53∗
PBIG
4×
CO
NN
ECT
ED(1
.80)
Pseu
doR
20.
25A
djus
ted
R2
0.13
Adj
uste
dR
20.
36N
2,99
3N
3,11
9N
1,12
4
Th
ista
ble
repo
rts
resu
lts
from
regr
essi
ng
earn
ings
man
agem
ent
(mod
el1)
,th
en
atur
allo
gari
thm
ofon
epl
usth
en
umbe
rof
anal
ysts
follo
win
gth
efi
rm(m
odel
2),
anal
yst
fore
cast
accu
racy
(mod
el3)
,acc
oun
tin
gst
anda
rdch
oice
(mod
el4)
,val
uati
on(m
odel
5),a
nd
equi
typr
icin
g(m
odel
6)on
firm
-leve
lan
dco
untr
y-le
velv
aria
bles
.Th
esa
mpl
ein
clud
esco
nn
ecte
dan
dn
onco
nn
ecte
dfi
rms
anal
yzed
inta
ble
3.E
xcep
tfo
rm
odel
2,w
hic
hin
clud
esye
ar,i
ndu
stry
,an
dco
untr
yef
fect
s,al
lot
her
mod
els
incl
ude
indu
stry
and
year
effe
cts.
Ben
eath
each
esti
mat
eis
repo
rted
the
robu
stt/
z-st
atis
tic
clus
tere
dat
both
the
coun
try
and
the
firm
leve
l.M
odel
4re
port
sth
em
argi
nal
effe
ctof
the
inte
ract
ion
term
and
the
mea
nin
tera
ctiv
eef
fect
usin
gth
em
eth
odol
ogy
prop
osed
byA
ian
dN
orto
n[2
003]
.∗∗
∗ ,∗∗
,an
d∗
den
ote
stat
isti
cal
sign
ifica
nce
atth
e1%
,5%
,an
d10
%le
vels
,re
spec
tive
ly,
base
don
two-
side
dte
sts.
Th
ede
fin
itio
ns
and
data
sour
ces
for
the
vari
able
sar
eou
tlin
edin
tabl
eA
1.
144 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
as: (�total current assets – �cash) – (�total current liabilities – �short-term debt –�taxes payable) – depreciation expense (see table A1 for more details)—on thepredicted probability of Big 4 auditors (PBIG4). Importantly, relying onLeuz, Nanda, and Wysocki [2003] specification minimizes data attritionin our sample. In addition to our test variables, we include several firm-and country-level controls in this regression: firm size (SIZE), cross-listing(CROSS-LISTING), profitability (ROA), firm growth (GROWTH), firm lever-age (LEVERAGE), the ownership stake of the largest shareholder (LARGE-OWN), state ownership (STATEOWN), a composite securities regulation in-dex (SECREG), law and order (LAWORDER), stock market development(STOCKTRAD), and investor protection (ANTISELF). All variables are de-fined in table A1. The results in model 1 include that the coefficient on theinteraction between PBIG4 and CONNECTED is negative and statisticallysignificant at the 1% level, implying that earnings management is lowerin politically connected firms with Big 4 auditors. In this regression, CON-NECTED is positive and statistically significant at the 1% level, suggestingthat earnings management is worse in politically connected firms. This re-sult reconciles with Chaney, Faccio, and Parsley’s [2011] evidence that po-litically connected firms exhibit lower earnings quality. Lending supportto the prediction in H4, our evidence implies that this effect is less pro-nounced in politically connected firms that appoint a Big 4 auditor.
We extend our analysis to consider three measures of firm-level trans-parency examined in recent research (e.g., Lang and Maffett [2011], Lang,Lins, and Maffett [2012]). This includes analyzing in model 2 the numberof analysts following a firm (ANALYSTS). Lang, Lins, and Maffett [2012]hold that greater analyst coverage and forecast accuracy are likely to reflectgreater transparency in the firm’s information environment. Besides ourtest variables, we include a set of controls motivated by prior research (e.g.,Lang, Lins, and Miller [2003, 2004]): firm size (SIZE); cross-listing (CROSS-LISTING); the ownership stake of the largest shareholder (LARGEOWN);state ownership (STATEOWN); firm growth (GROWTH); the standard devi-ation of monthly returns over the previous year (VARIANCE); earnings sur-prise (EARNINGS SURPRISE); as well as industry, year and country effects.We find a negative and statistically significant (at the 5% level) coefficienton CONNECTED, indicating that connected firms have lesser analyst cov-erage. In additional evidence supporting the prediction in H4, we provideevidence at the 5% level that this effect subsides for politically connectedfirms that are Big 4 clients.
In model 3, we complement the evidence in model 2 by analyzingforecast accuracy (ACCURACY), defined as the negative absolute value ofthe difference between the median forecast and the actual earnings pershare (EPS) deflated by the stock price after Lang and Lundholm [1996]and Hope [2003]. We follow Hope’s [2003] cross-country research by in-cluding these control variables in the regression: firm size (SIZE); analystfollowing (ANALYSTS); cross-listing (CROSS-LISTING); an indicator vari-able for loss firms (NEG EARNINGS); the absolute value of the change in
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 145
earnings over the previous year (CHANGE EARNINGS); as well as country-level measures for earnings management (EARNINGS MGN), the quality offinancial reporting (CIFAR), domestic listed firms (LISTED FIRMS), in-vestor protection (ANTISELF), Hofstede’s [2001] cultural dimensions un-certainty avoidance (UAI) and individualism (IDV), along with industry andyear effects. Consistent with Chen, Ding, and Kim. [2010], the results inmodel 3 suggest that political connections adversely affect analyst forecastaccuracy. Importantly for our purposes, we find that the coefficient on theinteraction term PBIG4∗CONNECTED is positive and statistically significantat the 1% level, suggesting that connected firms that appoint a Big 4 auditorbenefit from more accurate analyst earnings forecasts.
In model 4, we develop another conditioning variable by identify-ing whether a firm adopts international accounting standards (IAS). Ac-counting quality is generally higher for these firms according to Barth,Landsman, and Lang [2008] and Lang and Maffett [2011]. In this re-gression, we follow prior research (e.g., Hope, Jin, and Kang [2006],Barth, Landsman, and Lang [2008], Kim and Shi [2012]) by control-ling for firm size (SIZE), the ownership stake of the largest shareholder(LARGEOWN), firm growth (GROWTH), firm leverage (LEVERAGE), cashflows from operating activities (CF), cross-listing (CROSS-LISTING), salesturnover (TURNOVER), level of financing activities (FINANCING), foreignsales (FOREIGNSALES), the logarithm of GDP per capita (LGDPC), investorprotection (ANTISELF), stock market development (STOCKTRAD), and acountry’s quality of financial reporting (CIFAR) as well as industry and yearfixed effects. Reinforcing our earlier evidence, the results indicate that thecoefficient on CONNECTED is significantly negative while the mean inter-active effect of PBIG4∗CONNECTED loads positively at the 5% level. Col-lectively, these results support that the presence of a high-quality auditormitigates the lower transparency of politically connected firms.
We consider in model 5 the role that auditor choice plays in shapingfirm value, measured by the market-to-book ratio (MTB). In this regression,we include other factors shown in prior research to affect firm value (e.g.,Durnev and Kim [2005]): firm size (SIZE), cross-listing (CROSS-LISTING),firm growth (GROWTH), the ownership stake of the largest shareholder(LARGEOWN), foreign sales to total assets (FOREIGNSALES), capital expen-ditures (CAPEX), and investor protection (ANTISELF) in addition to yearand industry fixed effects. We report that the coefficient on the interactionbetween PBIG4 and CONNECTED loads positively at the 5% level, implyingthat connected firms that appoint a Big 4 auditor are valued at a premium.This finding extends evidence in Fan and Wong [2005] that the economicconsequences of the presence of a high-quality auditor are larger for EastAsian firms with highly concentrated control.
Recent research suggests that accounting transparency at the country-(e.g., Hail and Leuz [2006]) and firm-level (e.g., El Ghoul, Guedhami,and Pittman [2012]) is associated with a lower cost of equity capital. Ac-cordingly, we extend our analysis in model 6 by gauging the links among
146 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
political connections, auditor choice, and equity pricing. We follow exten-sive prior research by using analysts’ earnings forecasts and stock pricesto derive the ex ante cost of equity (e.g., Hail and Leuz [2006], Dhaliwal,Heitzman, and Li [2006], Chen, Chen, and Wei [2011]). This approachconstitutes a useful alternative given the failure of asset pricing models toproxy for the cost of equity (e.g., Fama and French [1997], Pastor, Sinha,and Swaminathan [2008]). More specifically, we adopt four implied costof equity capital models, namely those developed by Gebhardt, Lee, andSwaminathan ([2001]; KGLS), Claus and Thomas ([2001]; KCT), Ohlsonand Juettner-Nauroth ([2005]; KOJN), and Easton ([2004]; KES). To reduceconcerns that the results are driven by the assumptions underpinning anyparticular model, we specify as the dependent variable the median impliedcost of equity obtained from the four models (KMED). Moreover, to allevi-ate the concern that optimism inherent in analysts’ earnings forecasts ad-mits bias that inflates the equity premium estimates, we follow Hail andLeuz [2006] by running a weighted least square regression that assignsless (more) weight to inaccurate (precise) forecasts. In this regression, theweight is equal to the forecast error (absolute value one-year ahead earn-ings forecast minus realized earnings deflated by assets per share).
In addition to our test variables, we include several control variables: thenatural logarithm of total assets (SIZE), the market value of common equityplus book value of debt scaled by total assets (MTB), forecast error definedas the difference between the one-year-ahead earnings forecast and real-ized earnings deflated by beginning of the period assets per share (FBAIS),the volatility of stock returns over the previous 12 months (VARIANCE),the realized inflation rate over the next year (INFLATION), disclosure stan-dards (DISCLOSE), law and order (LAWORDER), and macroeconomic vari-ability (MACVAR). In model 6, which also includes year and industry fixedeffects, we observe a negative and statistically significant (at the 1% level)coefficient on the interaction between PBIG4 and CONNECTED, implyingthat connected firms that appoint a Big 4 auditor attract cheaper equityfinancing.
Notwithstanding that the implied cost of capital approach has beenwidely used in the accounting and finance literature (see, e.g., Hail andLeuz [2006], Chen, Chen, and Wei [2011]), it is beset by another limita-tion apart from deviations between analysts’ and investors’ earnings expec-tations. This limitation relates to the sensitivity of the implied cost of equityestimates to the assumptions of long-term growth rates beyond analysts’forecast horizons (e.g., Easton [2004]). In particular, the cost of equity es-timates derived from the models of Claus and Thomas [2001] and Ohlsonand Juettner-Nauroth [2005] assume that the perpetual growth rate is equalto the future (realized) inflation rate. To verify that our findings in model6 are robust to addressing this concern, we follow Hail and Leuz [2006] byre-estimating the median cost of equity capital (KMED) after applying thesealternative growth assumptions for the models of Claus and Thomas [2001]and Ohlson and Juettner-Nauroth [2005]: (i) a constant long-run growth of
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 147
3% and (ii) a perpetual growth rate equal to the annual real GDP growthplus long-run inflation rate, respectively. The untabulated results includethat the PBIG4∗CONNECTED coefficient is negative and statistically signif-icant at the 5% level, corroborating our earlier evidence that politicallyconnected firms with Big 4 auditors enjoy equity financing costs that arecloser to the risk-free rate. Overall, the evidence reported in this sectionprovides empirical support for our fourth hypothesis that politically con-nected firms with Big 4 auditors exhibit lower earnings management andgreater transparency, and benefit from higher valuations as well as cheaperequity financing costs.
5. Conclusions
In response to calls for research on this issue (e.g., Wang, Wong, and Xia[2008]), we examine the importance of corporate insiders’ political con-nections, which exacerbate the expropriation of minority investors accord-ing to recent evidence (e.g., Faccio [2006], Qian, Hongbo Pan, and Yeung[2011]), to auditor choice in public firms worldwide. The tension that con-nected insiders experience in deciding whether to appoint a Big 4 auditorto constrain their discretion over financial reporting motivates our analysis.In one direction, insiders eager to persuade outside investors that they arenot exploiting their political connections to divert corporate resources mayrely on a Big 4 auditor to strengthen external monitoring. In the other di-rection, connected insiders depriving outside investors may prefer to hirea non–Big 4 auditor to help conceal their diversion by rendering the finan-cial statements less informative about underlying firm performance. Usinga unique data set on political connections around the world constructed byFaccio [2006], we analyze which financial reporting incentive dominates byestimating the role that political connections play in auditor choice. Ourevidence that public firms with political connections are more likely to ap-point a Big 4 auditor lends support to the intuition that these firms respondto the serious agency problems that connections engender by improving ac-counting transparency evident in auditor choice.
Next, we separately isolate whether connected firms with ownershipstructures conducive to self-dealing by insiders or operating in countrieswith relatively poor institutional infrastructure are even more eager to re-duce information asymmetry by engaging a Big 4 auditor. In a set of re-sults consistent with these predictions, we find that the link between au-ditor choice and political connections is stronger when firms’ ownershipcharacteristics lead to severe agency conflicts and country-level governanceinstitutions are worse. This evidence implies that Big 4 auditors in thesesituations are more valuable for protecting outside investors by disciplininginsiders against diverting corporate resources.
Finally, we consider some economic outcomes stemming from auditorchoice in politically connected firms. This analysis contributes to resolvingwhat is behind our evidence that connected firms have greater demand
148 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
for Big 4 auditors. We begin by documenting that connected firms thatappoint Big 4 auditors exhibit lower earnings management and greatertransparency evident in analyst coverage and forecast accuracy as well asthe adoption of international accounting standards. Additional evidenceimplies that the capital markets reward connected firms that are Big 4clients with higher valuations and cheaper equity financing costs. Impor-tantly, despite that our core results persist when we tackle this issue withseveral standard techniques—including various matching procedures, es-timating a treatment effects model, controlling for firm heterogeneity inrandom effects models, and narrowing our analysis to firms with long au-ditor tenure—we stress that we cannot dismiss endogeneity as a competingexplanation for our evidence.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 149
TA
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150 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
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AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 151
TA
BL
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1—C
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Vari
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Defi
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Polit
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152 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
TA
BL
EA
1—C
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Vari
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Defi
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rnat
ion
alC
oun
try
Ris
kG
uide
STO
CK
TR
AD
Stoc
km
arke
ttot
alva
lue
trad
eddi
vide
dby
GD
P.B
eck,
Dem
irgu
c-K
unt,
and
Lev
ine
[200
9]B
AN
KD
EPT
he
tota
lval
ueof
dem
and,
tim
e,an
dsa
vin
gde
posi
tsat
dom
esti
cde
posi
tm
oney
ban
ksas
ash
are
ofG
DP.
Inte
rnat
ion
alFi
nan
cial
Stat
isti
cs
FIN
SYSD
EPD
eman
d,ti
me,
and
savi
ng
depo
sits
inde
posi
tmon
eyba
nks
and
oth
erfi
nan
cial
inst
itut
ion
sas
ash
are
ofG
DP.
Inte
rnat
ion
alFi
nan
cial
Stat
isti
cs
JUD
ICIA
LA
sses
smen
toft
he
effi
cien
cyan
din
tegr
ity
ofth
ele
gale
nvi
ron
men
tas
itaf
fect
sbu
sin
ess,
part
icul
arly
fore
ign
firm
s,pr
oduc
edby
the
coun
try
risk
rati
ng
agen
cyB
usin
ess
Inte
rnat
ion
alC
orp.
Itm
aybe
take
nto
repr
esen
tin
vest
ors’
asse
ssm
ento
fcon
diti
ons
inth
eco
untr
yin
ques
tion
.Ave
rage
betw
een
1980
and
1983
.Th
esc
ale
ran
ges
from
0to
10w
ith
low
ersc
ores
repr
esen
tin
glo
wer
effi
cien
cyle
vels
.
La
Port
a,L
opez
-de-
Sila
nes
,an
dSh
leif
er[2
006]
RES
TR
ICT
ION
SA
regu
lato
rysc
ore
con
stru
cted
base
don
regu
lati
ons
that
proh
ibit
orse
tlim
its
onth
ebu
sin
ess
acti
viti
esof
publ
icof
fici
als.
Facc
io[2
006]
CIF
AR
Inde
xcr
eate
dby
exam
inin
gan
dra
tin
gco
mpa
nie
s’19
95an
nua
lrep
orts
onth
eir
incl
usio
nor
omis
sion
of90
item
s.T
hes
eit
ems
fall
into
seve
nca
tego
ries
:gen
eral
info
rmat
ion
,in
com
est
atem
ents
,bal
ance
shee
ts,f
unds
flow
stat
emen
t,ac
coun
tin
gst
anda
rds,
stoc
kda
ta,a
nd
spec
iali
tem
s.A
min
imum
ofth
ree
com
pan
ies
inea
chco
untr
yw
ere
stud
ied.
See
Bus
hm
an,
Piot
rosk
i,an
dSm
ith
[200
4].
La
Port
a,L
opez
-de-
Sila
nes
,an
dSh
leif
er[2
006]
(Con
tinue
d)
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 153
TA
BL
EA
1—C
ontin
ued
Vari
able
Defi
nit
ion
Sour
ce
RU
LEO
FLAW
Mea
sure
sth
eex
ten
tto
wh
ich
agen
tsh
ave
con
fide
nce
inan
dab
ide
byth
eru
les
ofso
ciet
y.T
hes
ein
clud
epe
rcep
tion
sof
the
inci
den
ceof
both
viol
enta
nd
non
viol
entc
rim
e,th
eef
fect
iven
ess
and
pred
icta
bilit
yof
the
judi
ciar
y,an
dth
een
forc
eabi
lity
ofco
ntr
acts
.See
Kau
fman
n,K
raay
,an
dM
astr
uzzi
[200
8].
La
Port
aet
al.[
2006
]
LIS
TED
FIR
MS
Th
en
umbe
rof
dom
esti
clis
ted
firm
sdi
vide
dby
popu
lati
onin
2000
.Am
easu
reof
the
impo
rtan
ceof
the
stoc
km
arke
t.L
aPo
rta,
Lop
ez-d
e-Si
lan
es,a
nd
Shle
ifer
[200
6]M
AC
VAR
MA
CVA
Ris
the
firs
tpri
nci
palc
ompo
nen
toff
our
prox
ies
for
mac
roec
onom
icva
riab
ility
:(i)
the
coun
try-
year
med
ian
stan
dard
devi
atio
nof
ann
uale
arn
ings
per
shar
eov
erth
ela
stfi
veye
ars
scal
edby
tota
lass
ets
per
shar
e,(i
i)th
eco
untr
y-ye
arm
edia
nst
anda
rdde
viat
ion
ofac
coun
tin
gre
turn
son
equi
tyov
erth
ela
stfi
veye
ars,
(iii)
the
stan
dard
devi
atio
nof
the
resi
dual
sfr
oma
regr
essi
onof
ann
ualg
ross
dom
esti
cpr
oduc
tgro
wth
rate
son
ati
me
inde
xov
erth
esa
mpl
ing
peri
od,a
nd
(iv)
the
coef
fici
ento
fvar
iati
onof
year
lyav
erag
eex
chan
gera
tes
(US$
tolo
calc
urre
ncy
)ov
erth
esa
mpl
ing
peri
od.
Aut
hor
s’ca
lcul
atio
ns
IDV
Apr
efer
ence
for
alo
osel
ykn
itso
cial
fabr
icor
anin
depe
nde
nt,
tigh
tly
knit
fabr
ic.
Hof
sted
e[2
001]
UA
IT
he
degr
eeto
wh
ich
peop
lefe
elun
com
fort
able
wit
ham
bigu
ity
and
anun
cert
ain
futu
re.
Hof
sted
e[2
001]
PRED
ATIO
NA
nin
dex
that
inco
rpor
ates
mul
tipl
eat
trib
utes
capt
urin
gth
eef
fect
iven
ess
ofin
stit
utio
nal
and
polit
ical
syst
ems
incu
rbin
ggo
vern
men
text
orti
on.
Dur
nev
and
Fauv
er[2
009]
EXPR
OPR
IAT
ION
Ass
essm
ento
fth
eri
skof
am
odifi
cati
onin
aco
ntr
actt
akin
gth
efo
rmof
are
pudi
atio
n,p
ostp
onem
ent,
orsc
alin
gdo
wn
due
tobu
dget
cutb
acks
,in
dige
niz
atio
npr
essu
re,a
chan
gein
gove
rnm
ent,
ora
chan
gein
gove
rnm
ente
con
omic
and
soci
alpr
iori
ties
.Th
isva
riab
leis
reco
ded
tova
rybe
twee
n0
to10
wit
hh
igh
ersc
ores
indi
cati
ng
grea
ter
risk
ofex
prop
riat
ion
.
La
Port
aet
al.[
1998
]
(Con
tinue
d)
154 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
TA
BL
EA
1—C
ontin
ued
Vari
able
Defi
nit
ion
Sour
ce
EAR
NIN
GS
MG
NA
ggre
gate
earn
ings
man
agem
ents
core
:th
eav
erag
era
nk
acro
ssfo
urm
easu
res,
EM
1–E
M4.
EM
1is
the
coun
try’
sm
edia
nra
tio
ofth
efi
rm-le
vels
tan
dard
devi
atio
ns
ofop
erat
ing
inco
me
and
oper
atin
gca
shfl
ow(b
oth
scal
edby
lagg
edto
tala
sset
s).E
M2
isth
eco
untr
y’s
Spea
rman
corr
elat
ion
betw
een
the
chan
gein
accr
uals
and
the
chan
gein
cash
flow
from
oper
atio
ns
(bot
hsc
aled
byla
gged
tota
lass
ets)
.EM
3is
the
coun
try’
sm
edia
nra
tio
ofth
eab
solu
teva
lue
ofac
crua
lsan
dth
eab
solu
teva
lue
ofth
eca
shfl
owfr
omop
erat
ion
s.E
M4
isth
en
umbe
rof
‘‘sm
allp
rofi
ts’’
divi
ded
byth
en
umbe
rof
‘‘sm
all
loss
es’’
for
each
coun
try.
Leu
z,N
anda
,an
dW
ysoc
ki[2
003]
DIS
CL
OSE
An
asse
ssm
ento
fdis
clos
ure
requ
irem
ents
rela
tin
gto
:(i)
pros
pect
us;(
ii)co
mpe
nsa
tion
ofdi
rect
ors
and
key
offi
cers
;(iii
)ow
ner
ship
stru
ctur
e;(i
v)in
side
own
ersh
ip;(
v)co
ntr
acts
outs
ide
the
ordi
nar
yco
urse
ofbu
sin
ess;
and
(vi)
tran
sact
ion
sbe
twee
nth
eis
suer
and
its
dire
ctor
s,of
fice
rs,a
nd/
orla
rge
shar
ehol
ders
.Th
ein
dex
ran
ges
from
0to
1,w
ith
hig
her
valu
esin
dica
tin
gm
ore
exte
nsi
vedi
sclo
sure
requ
irem
ents
.
La
Port
a,L
opez
-de-
Sila
nes
,an
dSh
leif
er[2
006]
SUE
AU
DIT
OR
Inde
xof
the
proc
edur
aldi
fficu
lty
inre
cove
rin
glo
sses
from
the
audi
tor
ina
civi
llia
bilit
yca
sefo
rlo
sses
due
tom
isle
adin
gst
atem
ents
inth
eau
dite
dfi
nan
cial
info
rmat
ion
acco
mpa
nyi
ng
the
pros
pect
us.E
qual
son
ew
hen
inve
stor
sar
eon
lyre
quir
edto
prov
eth
atth
eau
dite
dfi
nan
cial
info
rmat
ion
acco
mpa
nyi
ng
the
pros
pect
usco
nta
ins
am
isle
adin
gst
atem
ent.
Equ
als
two-
thir
dsw
hen
inve
stor
sm
usta
lso
prov
eth
atth
eyre
lied
onth
epr
ospe
ctus
and/
orth
atth
eir
loss
was
caus
edby
the
mis
lead
ing
acco
unti
ng
info
rmat
ion
.E
qual
son
e-th
ird
wh
enin
vest
ors
mus
tals
opr
ove
that
the
audi
tor
acte
dw
ith
neg
ligen
ce.E
qual
sze
roif
rest
itut
ion
from
the
audi
tor
isei
ther
unav
aila
ble
orth
elia
bilit
yst
anda
rdis
inte
nto
rgr
oss
neg
ligen
ce.
La
Port
a,L
opez
-de-
Sila
nes
,an
dSh
leif
er[2
006]
LG
DPC
Th
en
atur
allo
gari
thm
ofth
eco
untr
y’s
GD
Ppe
rca
pita
den
omin
ated
inU
Sdo
llars
.W
orld
Dev
elop
men
tIn
dica
tors
[200
8]
FDI
Fore
ign
dire
ctin
vest
men
tdiv
ided
byG
DP.
Wor
ldD
evel
opm
entI
ndi
cato
rs[2
008]
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 155
T A B L E A 2Means for Country Level Institutional Infrastructure Variables
Country RESTRICTIONS EXPROPRIATION ANTISELF PROTECTION
Austria 2.00 0.31 0.21 0.10Belgium 0.00 0.37 0.54 0.07Canada 2.00 0.33 0.64 0.96Chile 2.00 2.50 0.63 0.61Denmark 1.00 0.33 0.46 0.36Finland 1.00 0.33 0.46 0.47France 2.00 0.35 0.38 0.47Germany 2.00 0.10 0.28 0.00Greece 4.00 2.88 0.22 0.32Hong Kong 1.00 1.71 0.96 0.85India 0.00 2.25 0.58 0.77Indonesia 0.00 2.84 0.65 0.51Ireland 4.00 0.33 0.79 0.48Israel 4.00 1.75 0.73 0.59Italy 0.00 0.65 0.42 0.20Japan 0.00 0.33 0.50 0.42Korea, South 1.00 1.69 0.47 0.36Malaysia 0.00 2.05 0.95 0.73Mexico 0.00 2.71 0.17 0.10Philippines 6.00 4.78 0.22 0.81Singapore 3.00 0.70 1.00 0.77Spain 3.00 0.48 0.37 0.55Sweden 1.00 0.60 0.33 0.39Switzerland 2.00 0.02 0.27 0.30Taiwan 0.00 0.88 0.57 0.55Thailand 3.00 2.58 0.81 0.37United Kingdom 2.00 0.29 0.95 0.78United States 4.00 0.02 0.65 1.00
This table reports the means for the four conditioning variables capturing countries’ governanceinstitutions.
156 O. GUEDHAMI, J. A. PITTMAN, AND W. SAFFAR
TA
BL
EA
3C
orre
latio
nsB
etw
een
the
Mai
nR
egre
ssio
nVa
riab
les
BIG4
CONNECTED
LARGEOWN
STATEOWN
COMPLEXITY
FOREIGNSALES
FINANCING
CROSS-LISTING
SIZE
ROA
LEVERAGE
GROWTH
INV
FDI
LGDPC
CO
NN
ECT
ED0.
06LA
RG
EO
WN
0.00
0.01
STAT
EO
WN
–0.1
3–0
.04
0.15
CO
MPL
EX
ITY
–0.0
20.
050.
02–0
.08
FOR
EIG
NSA
LES
0.11
0.04
–0.0
5–0
.05
–0.0
2FI
NA
NC
ING
–0.0
4–0
.02
0.01
–0.0
3–0
.06
0.00
CR
OSS
-LIS
TIN
G0.
090.
10–0
.11
–0.0
20.
000.
13–0
.03
SIZE
0.11
0.04
0.06
0.11
0.15
–0.1
6–0
.13
0.16
RO
A0.
110.
020.
080.
010.
040.
040.
040.
020.
11LE
VER
AG
E0.
020.
110.
00–0
.03
0.04
0.03
0.07
0.05
0.20
–0.0
5G
RO
WT
H–0
.05
–0.0
40.
020.
03–0
.08
0.00
0.42
–0.0
20.
000.
240.
00IN
V–0
.04
–0.0
90.
04–0
.05
0.09
0.08
–0.0
6–0
.07
–0.1
00.
09–0
.14
–0.0
4FD
I0.
060.
030.
02–0
.03
–0.0
90.
190.
080.
03–0
.39
0.03
–0.0
30.
070.
02LG
DPC
0.15
–0.2
3–0
.27
–0.2
3–0
.08
0.19
–0.0
30.
06–0
.19
–0.0
6–0
.04
–0.0
7–0
.05
0.08
SUE
AU
DIT
OR
0.07
–0.0
8–0
.24
0.01
0.06
0.05
–0.0
2–0
.01
–0.0
3–0
.02
–0.1
5–0
.04
0.08
0.01
0.16
Th
ista
ble
repo
rts
corr
elat
ion
sfo
rth
ere
gres
sion
vari
able
sw
hile
allo
win
gfo
rco
untr
yan
dfi
rmle
vel
clus
teri
ng
for
asa
mpl
eof
1,37
1po
litic
ally
con
nec
ted
firm
san
d1,
911
non
con
nec
ted
firm
sfr
om28
coun
trie
s.B
oldf
ace
indi
cate
sst
atis
tica
lsig
nifi
can
ceat
the
1%le
vel.
Th
ede
fin
itio
ns
and
data
sour
ces
for
the
vari
able
sar
eou
tlin
edin
tabl
eA
1.
AUDITOR CHOICE IN POLITICALLY CONNECTED FIRMS 157
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