family firm executice compensation
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Promotion Incentives and Executive Compensation in Family Firms
Thomas BatesRichard Ivey School Of Business
University of Western OntarioLondon, Ontario, N6A3K7
Tomas JandikKatz Graduate School of Business
University of PittsburghPittsburgh, PA, 15260
Kenneth LehnKatz Graduate School of Business
University of PittsburghPittsburgh, PA, 15260
March 2000
Submitted to the research conference jointly sponsored byTuck’s Center for Corporate Governance
andThe Journal of Financial Economics
at the Tuck School of Business at Dartmouth
July 7-8, 2000
The authors would like to thank Kevin Murphy and seminar participants at the 1999 American EconomicAssociation annual meetings for their comments and suggestions.
Promotion Incentives and Executive Compensation in Family Firms
Abstract
Family firms are the predominant form of business organization throughout the world, yet littleis known about the types of incentive problems these firms face and how they are resolved.This paper examines a particular incentive problem, the dampening of promotion incentives, infamily firms in which children succeed parents as president, chief executive officer, or chairman.The relatively young age of the successor child, combined with the family’s voting control,diminishes the promotion incentives for non-family, senior managers in the firms. This hasimplications for the level and structure of executive compensation in these firms.
As tournament theory predicts, the level of compensation for top officers of family firms issignificantly lower than it is for the corresponding officers in nonfamily firms. Relatedly, theinter-rank spread in compensation levels of top officers and non-family senior managers issignificantly smaller for family firms than it is for nonfamily firms. The results are consistentwith the hypothesis that there is less of a “prize component” in the compensation levels of topofficers of family firms than there is in nonfamily firms that rely more on tournaments as anincentive device.
We also examine whether family firms rely more on incentive compensation for non-familysenior managers as a substitute for diminished promotion incentives. Family firms relysignificantly less on executive stock options than the control firms, presumably because they donot want to dilute the family’s control. Among family firms, however, those with dual classesof common stock rely significantly more on executive stock options, suggesting that low votingstock serves as an important compensation device in family firms. Finally, no significantdifference exists in performance-based cash bonuses paid to senior managers of family versuscontrol firms. Overall, the results show that the level and structure of executive compensation isdifferent for family firms than it is for other firms. To a large degree, however, the ways inwhich family firms resolve their incentive problems remains a puzzle.
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1. Introduction
This paper examines incentive issues for a unique set of firms -- family firms in which
children succeed parents as the firms’ presidents, chief executive officers, or chairmen. Since
children usually ascend to these positions when they are young, and since families control the
firms, children have a long expected tenure as the top officers in these firms. This creates a
potentially thorny incentive problem, since it diminishes the promotion incentives facing senior
managers who are not members of the controlling family.
We focus on how the structure and level of executive compensation in family firms is
affected by the diminished promotion incentives facing non-family executives. Specifically, we
examine two sets of issues. First, these firms provide a unique setting for testing the tournament
theory of executive compensation. Since there is a high ex ante probability that the child will be
selected as the heir apparent to the top position in these family firms, any tournament effectively
ends at the senior vice-president level for the non-family managers of these firms. This leads to
several testable hypotheses under the tournament theory. First, the prize component associated
with the top position in these family firms should be less than it is in other similar, but non-
family, firms. Second, prior to succession, the level of compensation for non-family managers at
the senior vice president level should be higher than that of similar level managers in non-family
firms. Finally, the difference in the level of compensation between top managers and senior VPs
should be lower than it is in other, non-family firms.
The paper also examines the use and form of incentive compensation for senior managers of
family firms. Diminished promotion incentives in family firms suggest that these organizations
should rely more on substitute incentive mechanisms, such as performance sensitive
compensation plans. While a major component of incentive compensation consists of stock
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option grants, the families’ desire to retain control over the firm’s voting rights makes this an
unlikely margin on which compensation is adjusted. It is more likely that an adjustment will
occur on other margins that strengthen incentives without diluting the families’ equity control,
such as cash bonuses, grants of phantom stock, or option grants of non-voting or low voting
shares in firms with dual classes of common stock.
We find significant differences in the level and structure of executive compensation for a
sample of 34 publicly traded family firms versus a control sample of firms matched on size and
industry. First, the difference in total compensation between top managers and their direct
subordinates is significantly lower in family firms as compared with the control firms. Further
investigation reveals that this difference is attributable primarily to significantly lower cash
compensation for top managers, rather than higher compensation of senior, non-family
managers. This result is consistent with the prediction that the prize component of “winning” a
top job in a family firm is lower than it is in other firms.
Second, we find that the proportion of executive compensation accounted for by stock option
grants is significantly lower in family firms than it is in other firms. This result is consistent
with the argument that families are reluctant to grant stock options for fear of diluting the
family’s control. Further support for this argument is found in the fact that stock options are
used substantially more in family firms with two classes of common stock, where the non-family
executives can be granted options on the low voting stock without diluting family control.
Finally, we find that family firms use cash bonuses based on accounting measures of
performance for senior managers, especially those who are not president, CEO, or chairman,
slightly more than the control firms, but this difference is not statistically significant.
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The paper contributes to the literature in several ways. First, it provides additional evidence
on the hierarchical incentives associated with promotion in organizations. The parent-child
succession pattern in our family firms provides a unique setting in which these promotion
incentives are truncated at the senior vice president level, and can be compared to similar firms
that lack such promotion constraints. Second, many of our findings regarding promotion
incentives in family firms can be extended to the more general case of firms run by young CEOs
and/or CEOs with voting control over the firm (e.g., large e-commerce firms with young CEOs
and concentrated ownership). Third, the paper provides evidence on the substitutability of
various forms of incentive compensation and hierarchical incentives. Finally, the paper is among
the first to explore executive compensation issues in family firms, which have received little
attention in the academic literature, despite their predominance as the primary form of business
organization throughout the world.
2. Compensation in family firms: Theory and predictions
2.1 Tournament theory
The tournament theory of executive compensation proposed by Lazear and Rosen (1981) and
Rosen (1986) depicts promotion and wage outcomes as resulting from sequential elimination
tournaments within the firm. Succession in each stage of the tournament guarantees the winner a
predefined compensation contract, where promotion is based on the relative performance of the
competitors at a particular rung of the tournament. The prospect of receiving a promotion to a
more prestigious and higher paying position, and the option associated with further tournament
competition, is presumed to create stronger incentives for lower level managers to perform well
without the necessity of imposing extensive constraints on their behavior. Given finite and
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diminishing succession opportunities, however, managers competing at the higher rungs of an
organization’s tournament attribute a lower value on the option associated with further
competition. At the extreme the option has no value for those who compete in the final
tournament for the firm’s top management position. To provide an incentive for managers to
compete in this final tournament, Rosen (1986) argues that a significant difference exists
between the compensation of top managers and their immediate subordinates. This difference
includes a “prize” which causes compensation to diverge from the marginal product of the top
manager, but also serves to make the final promotion more attractive. Baker, Gibbs, and
Holmstrom (1994) provide a similar framework for hierarchical incentives, where promotions
within the organization are directly linked to increases in pay.
A few previous studies have examined the empirical validity of tournament theory within
firms. For example, Lambert, Larcker, and Weigelt (1993) analyze compensation data for 303
large, publicly traded U.S. industrial firms from 1982-1984. Consistent with tournament theory,
the authors find that the level of total compensation is a convex function of the employee’s
position within the firm’s hierarchy. They further find that even after controlling for the size of
the assets managed, executive compensation remains a positive function of the level of
employment in the organization. O’Reilly, Main, and Crystal (1988), analyzing data from
Business Week’s 1984 executive compensation survey, do not find evidence supporting the
tournament theory. Specifically these authors do not find that the difference in total
compensation between a firm’s CEO and its senior VPs is positively associated with the
competitiveness of the tournament (as proxied by the number of senior VPs).1
1 Tests of tournament theory have also been undertaken in the context of professional sports and individual effort.Ehrenberg and Bognanno (1990) and Becker and Huselid (1992) examine the role of prize money and competitorperformance in the settings of the European Professional Golf Tour and NASCAR racing circuit respectively.
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2.2 Compensation levels
In the family firms under study in this paper, the child is selected at a relatively young
age to lead the firm as president, CEO, or chairman. Combined with the fact that in all cases, the
families own a controlling stake in their firm’s voting equity shares, the expected tenure of the
child in the firm’s top position is quite long. This effectively precludes other senior managers
from landing the top job in these firms. In this case, any tournament in these firms effectively
ends one rung below where it ends in most other firms (i.e. at the senior VP level). Since, as a
practical matter there is no tournament for the top position in the family firm, there is little need
for a prize component to be embedded in the compensation of the firm’s top officer. As a result,
we predict that if tournament theory accurately depicts wage and promotion outcomes within the
firm, compensation of the top officers of family run firms should be lower than the compensation
received by the top officers in a matched sample of non-family firms.
A second prediction involves the compensation of senior managers one rung below the top
officers. Since these senior management positions are likely to represent the final round of the
tournament in family firms, the prize component embedded in the compensation of these
managers is expected to be higher than for their counterparts in non-family firms. In addition,
the senior managers of family firms must be compensated for the lack of promotion opportunity.
Otherwise, in equilibrium their services would be bid away by other firms that do offer an
additional “prize” for promotion to the firm’s top management position. Therefore, our second
prediction is that the level of compensation of senior managers, one rung below the top position,
is higher in family firms than it is in other firms.
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Finally, a third prediction emerges from the first two. Since the level of compensation is
predicted to be lower for top managers and higher for other senior managers in family firms, the
difference in the compensation levels between these two groups of managers is expected to be
smaller in family firms than in other firms.
2.3 Incentive compensation
Since family firms are the predominant form of business organization throughout the
world, at least in terms of number, we presume that they have solved the problem of dulled
promotion incentives associated with the long expected tenure of children as top officers in these
firms. In the absence of hierarchical incentives, we expect firms to adjust the incentives of non-
family senior management in other ways. The most obvious substitute for promotion incentives
is a greater reliance on incentive compensation.
Stock-based compensation plans are frequently employed as a method of aligning the
interests of managers to those of shareholders. Family firms may be reluctant to rely heavily on
stock-based compensation, however, since awards of stock and stock options may dilute their
voting control over the firm. DeAngelo and DeAngelo (1985) suggest that these concerns are
not unique to family-run firms, but also extend to the more general case of majority owner-
manager firms.
Family firms may solve their incentive compensation problem in two ways. First, as
suggested by DeAngelo and DeAngelo (1985), such firms may issue dual classes of common
stock so that stock-based compensation awards may be offered using only non-voting shares.
Family firms, concerned both with the diminution of promotion incentives and the dilution of
voting control, may also align the incentives of managers through the use of incentive
mechanisms that do not directly involve grants of stock or stock options, such as cash bonuses
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and phantom-stock allocations. Since these forms of incentive compensation are likely to be
close substitutes, we predict that family firms will rely more on dual class stock compensation,
cash bonuses, and phantom stock awards more than non-family firms.
3. Sample and data
Our sample consists of 34 publicly traded firms in which a child succeeded his parent as the
firm’s president, CEO, or chairman. We identified the sample in the following way. First, we
recorded all firms, excluding utilities and banks, listed in issues of Value Line during the fourth
quarter of 1997 in which the president, CEO, or chairman shared the same last name. We also
included firms in which the president, CEO or chairman shared the same last name as a
controlling stockholder in the company. We further required that the family control at least 25%
of the voting rights in the firm.2
After identifying these firms, we consulted Dun & Bradstreet’s for the birth dates of the two
people who shared the same last name. Firms were retained if the age difference between the
incumbent president, CEO, and/or chairman and his successor was at least 20 years. To identify
the year in which succession occurred, we consulted Moody’s Industrial and OTC Manuals.
After identifying this year, the Wall Street Journal Index was used to verify that a child had
indeed succeeded his parent as president, CEO, or chairman of the board. Once the year of
succession was identified, we attempted to obtain proxy statements for each of the six years
surrounding the year of succession for each firm in the sample (i.e. three years prior to, and three
years following the fiscal year of succession). In all, 45 firms were identified using the above
methodology. However, only 37 of the firms had the requisite proxy data to carry out the study.3
2 Given constraints on our ability to accurately measure all of the various family relationships, family members areidentified solely by a common last name.3 Proxy statements were collected using Lexis Nexus and the collection held by The Ohio State University.
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While this draft includes data for only 34 of the 37 sample firms, future versions of this research
will incorporate the complete sample.
For comparison purposes, each sample firm is matched to single publicly traded firm selected
on the basis of firm size and industry. Specifically, we identified all firms on Compustat that
shared the same SIC code as the family firm in the year of succession, under the constraint that at
least ten firms on Compustat satisfied this condition. If fewer than 10 firms could be identified,
we then identified potential control firms based on the first 3-digits of the SIC (2-digits if
necessary). Using this group of SIC match firms, we then selected the firm that was closest in
market value of equity to the sample firm at the end of the fiscal year in which succession
occurred. Proxy statements for each control firm were then obtained for the six years around the
sample firm’s year of succession. Thus far, compensation data has been extracted for 34 of the
37 matched pairs. It is these firms that comprise the sample for this draft of the paper.
Table 1 provides a brief summary of the matched pairs used in the paper. The table includes
the company names of the family and matched firms, as well as the last name of the controlling
family. Also included is the year of succession as well as the age of the child on the succession
date. The ages of successors range from 30 to 52. The mean and median age at succession is 39
and 38, respectively. The young age at which the children succeed their parents suggests that
these successors can expect to enjoy relatively long tenures as the firms’ top managers.
Brickley, Linck, and Coles (1999) find that the mean (median) age of successors for a sample of
CEOs appearing in the Forbes executive compensation surveys who left office between 1989 and
1993, was 51.6 (55.0) years, considerably older than the mean and median age of the child-
successors in our sample. As of the writing of this paper most of the child-successors continue
on as their firms’ senior managers, which makes it difficult to compare their average tenure to
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their counterparts in non-family firms. Currently the mean and median tenure of the children in
top management spots is nine and eight years, respectively.4
Summary statistics presented in table 2 reveal little difference in the mean size of the two
samples. This is expected since we matched the family firms on size. The mean book value of
assets is more than twice as large for the control firms than it is for family firms, but the
difference is not statistically significant. The median value of this variable is considerably
smaller than the mean value for both sets of firms, suggesting the presence of outliers in both
samples. The difference in median total assets is also not significantly different from zero.
Neither result is unexpected, of course, since we matched the family and control firms on another
size metric, the market value of equity.
Summary statistics for two performance measures are included in table 2. The first is the
market-to-book ratio, computed as the ratio of the market value of a firm’s assets (defined as the
sum of the book value of debt and preferred stock plus the market value of common equity) to
the book value of its assets. This measure, which also is used frequently as a proxy for growth
opportunities, does not differ significantly across the matched pairs of family and control firms.
The second performance measure is return on assets (ROA), defined as the ratio of operating
income to the book value of assets. Neither the mean or median values of ROA differ
significantly between the samples of family and control firms. While both performance
measures decline in the years following succession in family firms (with the exception of the
median market-to-book), similar performance declines are observed for the sample of control
4 Brickley, Linck, and Coles (1999) find that for a sample of CEOs appearing on the Forbes annual executivecompensation surveys who left office between 1989 and 1993, the average (median) tenure of these executives inthe CEO position was 9.6 (8.0) years.
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firms. None of the differences between the pre and post-succession intervals are significantly
different from zero.
Overall, the performance data suggests that family firms not only survive, but also effectively
solve the incentive problems described above. This evidence is consistent with the results of
Holderness and Sheehan (1988), who find that the performance of majority-owned firms is
indistinguishable from the performance of firms with more diffuse ownership.
We also document that the ownership structure of the two groups of firms differs
substantially. The mean percent of equity controlled by families in the sample of family firms is
39%. On average, outside blocks (i.e., blocks not represented on the board) own 8.1% of family
firms, versus 18% of the control firms. This difference is significant at the 0.01 level. The
percentage of equity held by officers and directors is 35% for family firms versus 23% for the
control firms. This difference is significant at the 0.05 level. Similar results hold for the median
values of these variables.
4. Empirical results
4.1 Tournament predictions
As described in section 2, three predictions emerge from tournament theory for our sample.
First, the level of compensation for the top managers in our sample of family firms should be
lower than the corresponding level of compensation for top managers in other firms. Second,
the level of compensation for other senior managers in family firms should be higher than it is in
other firms. Third, the difference in compensation between the top managers and other senior
managers should be smaller in our sample of family firms than it is in other firms.
Results from empirical tests of these predictions are contained in tables 3, 4, and 5. In table 3
we report on the univariate differences in compensation variables between the family and control
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firms. In table 4 we report similar results decomposed by pre and post-succession periods.
Table 5 provides regression results illustrating the determinants of the various components of the
compensation contracts granted to the executives of the family and control firms.
The results in table 3 provide some support for the tournament theory. Mean and median
values of compensation are reported for two levels of managers. “Upper-level” managers are
defined as managers with the title of president, CEO, or chairman. “Lower-level” managers are
defined as other managers for whom compensation data is listed in the firm’s proxy statements.
The ascending child and/or other family members often serve in the lower level management
group, however, compensation awards to these individuals are excluded from the results that
follow.
The mean and median values of three compensation variables for the two samples are
reported in table 3. First, the table reports the mean and median values for cash compensation,
defined as the sum of the managers’ salary, bonus, and other cash compensation. Second, the
mean and median value of stock options granted to the managers is reported. Stock option grants
are valued using the Black-Scholes model with continuously paid dividends. Third, the mean
and median values of total compensation, defined as the sum of the cash and option components,
are reported in the table. All compensation data is reported in constant 1997 dollars.
Results in table 3 reveal that the mean and median levels of total compensation are lower for
the top managers of family firms than they are for the top managers in control firms. The
median level of total compensation for upper managers is $548,468 in family firms versus
$796,456 for the control firms. This difference is significant at the 0.10 level. This result is
consistent with the tournament theory prediction that the prize component of top executive
compensation should be smaller in family firm than in their control firms.
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No significant difference is found in the mean or median total compensation of lower level
managers across the two samples. Median total compensation of lower level managers in family
firms is actually lower than the corresponding value in control firms -- $285,161, versus
$386,156. This result is not consistent with the tournament theory prediction that the
compensation of lower level managers should be significantly higher in the family firms, where
these managers have little prospect of ascending to the top position.
Table 3 also reports the mean and median percent differences in the total compensation of
upper versus lower level managers across the two samples. The median value of the “inter-rank”
spread in total compensation is 71% for the family firms versus 86% for the control firms. This
difference, which is significant at the 0.10 level, is consistent with the tournament theory
prediction. The result is driven completely by lower total compensation for upper level
managers in family firms and not by higher total compensation for lower level managers in these
firms.
A somewhat different picture emerges for the differences in cash compensation of upper
versus lower managers between the two groups of firms. No significant differences exist in the
mean and median levels of cash compensation for upper and lower managers in the family and
control firms. The median percent difference in cash compensation for upper versus lower
managers, however, is lower for family firms (69%) than it is for their control firms (95%), a
difference that is significant at the 0.01 level. Similar differences in mean cash compensation are
also significant. To the extent that the prize component of compensation manifests as a non-
contingent cash payment, this result is consistent with the tournament theory prediction.
Table 4 presents similar comparisons to those in table 3, decomposed into the three years
before and after the year of succession. Any uncertainty about the child’s ascension to the top
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position is resolved in the years following succession in family firms. Combined with the
ownership position of the controlling family, and the child’s lengthy expected tenure, the
tournament predictions are expected to be most observable in the years following succession.
However, Vancil (1987) suggests that a successor is often chosen several years before the actual
date of turnover in the top-management position. If so, the tournament is effectively over before
the year of succession. In this case, non-family senior managers of family firms are expected to
have compensation contracts in the three years before succession that look similar to contracts
granted after the child’s succession.
Consistent with this latter observation, we find that the level of total compensation is not
significantly different across the two groups of firms for lower level managers in years before
and after succession. For upper level managers, we find no significant difference in total
compensation before succession. However, after succession, the median level of compensation
for upper level managers of family firms is $517,501 versus $760,146 for their counterparts in
the control firms. This result is significant at the 0.10 level. Similar results hold for the mean
values of this variable.
The mean and median values of cash compensation are slightly higher for lower level
managers of family firms, than for the low level managers in the control firms, although this
difference is not significant. Conversely, the mean and median levels of cash compensation are
smaller for upper level managers in family firms as compared to their counterparts in the
matched control firms, but these differences are also not significantly different from zero. We do
find that the mean and median percent differences in cash compensation of upper versus lower
managers is significantly lower in the family firms compared to the matched control firms, but
only in the post-succession years. The median value of this “inter-rank” spread is 61% for
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family firms in the post-succession years, versus 102% for the control firms. This finding is
consistent with the prediction under tournament theory that the prize component associated with
winning the top job in a family firm should fall significantly after a young child is selected for
the firm’s top job. However, we cannot presently distinguish this interpretation from another,
more obvious explanation – the child who is selected is paid less than his predecessor who was
older and had a greater experience.
To control for other variables that might affect the difference in the compensation of upper
vs. lower managers, we estimate two sets of ordinary least squares regressions. In the first set we
regress the level of upper manager compensation on a series of independent variables, including
the level of lower manager compensation, firm size as measured by the natural log of equity
value, market-to-book ratio, and return on assets. We also include a dummy variable equal to
one if the firm is family run, as well as a dummy variable equal to one in post-succession years.
These regressions are estimated for equations in which both total compensation and cash
compensation are included as dependent variables. The results are presented in table 5A.
The regression equations reported in table 5A have respectable R-squareds, ranging from
0.46 to 0.53, largely because the average compensation of lower managers is included as an
independent variable. As expected, a highly significant and positive relation exists between the
average compensation of upper mangers and the corresponding measure for lower managers.
The coefficients associated with this variable range from 1.65 to 1.89 in the four equations
reported in table 5A, and all coefficients are significant at the 0.01 level. A family firm dummy
variable enters with a negative coefficient in all four equations, but it is statistically significant
only in the two cash compensation equations. Its coefficient in the two cash compensation
equations implies that the average cash compensation of top managers of family firms in which a
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child succeeds a parent is approximately $135,030 to $146,410 lower than it is in other firms.
The coefficient on the dummy variable for family firms in post-succession years is negative but
not significantly different from zero in the two equations in which it enters as an independent
variable.
Two additional variables enter significantly into the equations in table 5A. The natural log of
equity value has a positive coefficient in both the total and cash compensation equations.
Consistent with the results of Jensen and Murphy (1990), this indicates that the top managers of
large firms are paid more than their counterparts in smaller firms, even after controlling for the
level of lower management compensation. This suggests a higher relative marginal product of
top managers in large firms. In addition, it could be explained by a larger prize component in the
compensation of top managers in large firms. The latter interpretation is consistent with the
conjecture that larger firms are more likely to rely on tournaments as an incentive device. The
market-to-book ratio enters with a negative and significant coefficient in both the total and cash
compensation regressions. To the extent that this variable proxies for growth opportunities, this
is a surprising result, since the value of tournament competition would seem to be greater for
firms with good growth opportunities (Baker, Jensen, and Murphy (1988)).
In table 5B, we report the results from a second set of regressions in which the percent
difference in the compensation of upper versus lower level managers is used as the dependent
variable. The independent variables used in these regressions are identical to those employed in
the regressions in table 5A except for the average level of compensation for the firm’s lower
managers. The adjusted R-squareds are much lower for these regressions, ranging from 0.015 to
0.033. The variable of most interest, the dummy variable for family firms, enters with a negative
coefficient in all four equations, and is significant in three of the four, including the two cash
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compensation equations. In these two equations, the coefficients are –17.30 and –26.32,
revealing that the spread in cash compensation for upper versus lower managers is roughly 17%
to 26% lower in the sample of family firms. This result, is consistent with the predictions under
tournament theory. The dummy variable for family firms in the post-succession period is
negative, but not significantly different from zero. This latter finding makes it less likely that our
results are due to the relatively lower pay that a young and less experienced child can be
expected to receive in the post-succession years of our family firms.
4.2. Incentive compensation
As discussed in section 2, the diminished opportunities for senior, non-family, managers to
be promoted to the top position in family firms is likely to dampen their incentives compared
with those facing senior managers of other firms. In equilibrium, one would expect adjustments
on other margins to compensate for the lack of hierarchical incentives in family firms, including
a greater reliance on various forms of incentive compensation. Data in tables 3 and 4 allow us to
examine whether this is indeed the case.
Stock options
An obvious candidate as an adjustment in incentive compensation is a greater reliance on
option-based compensation. This adjustment, however, is unlikely to be attractive to a
controlling family, since stock option grants may dilute their voting control. The data in tables 3
and 4 reveal that option grants are far less common in our sample of family firms compared to
their control firms matched on size and industry.
Table 3 shows that the median value of option grants to lower level managers is higher for
the control firms ($64,621) than it is for the family firms ($20,519). This difference is
statistically significant at the 0.05 level. Similar results hold for the mean value of this variable,
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although these results are not significant. The median value of option grants also differs
significantly for upper level managers in the two groups of firms. The mean value of this
variable also differs for the two groups of upper managers, but not significantly. Less
dependence on option grants for the upper management of family firms is expected, as family
ownership makes the wealth of these managers substantially sensitive the value of the firm’s
shares.
The results on stock option grants are more striking when one examines the percent of total
compensation accounted for by stock option grants in family versus control firms. Table 3
shows that the median percent of total compensation accounted for by stock option grants is only
7.1% for lower level managers of family firms, versus 22.47% for their counterparts in control
firms. This difference is significant at the 0.05 level. Similar results hold for the mean values of
this variable. The median and mean values of this variable are also significantly lower for upper
level managers of family firms (2.43% and 12.44%, respectively) versus their counterparts in the
control sample (20.36% and 24.46%, respectively). Table 4 presents similar results for the pre
and post-succession years. The results generally show that in both periods, lower level managers
receive fewer stock option grants, both in dollar value and as a percent of total compensation, in
family firms versus their matched control firms. These differences are generally more significant
in the post-succession years.
The results on stock options are consistent with the view that family firms are reluctant to
grant stock options to non-family senior managers for fear of diluting the families’ control.
Family firms with dual classes of common stock with different voting rights can avoid this
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problem by granting stock options on the low voting stock to managers who are not members of
the family.5
Univariate data shows that family firms with dual classes of common stock use executive
stock options significantly more than other family firms, especially for lower level managers.
The median percent of total compensation accounted for by stock option grants for lower level
managers is 26.28% for the six family firms with dual classes of common stock, versus 5.23%
for family firms with only one class of common stock. This result is statistically significant at
the 0.05 level. Similar, but even stronger, results hold for the mean values of this variable. It is
worth noting that the family firms with dual classes of common stock use executive stock
options to roughly the same extent as the control firms. This suggests a potentially important
benefit of dual classes of common stock – its role as a compensation device.
Regression results on the relation between the use of executive stock options and dual classes
of common stock are reported in table 6. The dependent variables in the equations are the
percent of total compensation accounted for by stock option grants. One set of regressions
pertains to lower level managers and the other set pertains to upper level managers. Following
Smith and Watts (1992), we include firm size, as measured by the market value of equity, and
the market-to-book ratio as independent variables. We also include a dummy variable that takes
the value of 1 for family firms and 0 otherwise, as well as a dummy variable that takes the value
of 1 for family firms with a single class of common stock and 0 otherwise.
The results support the univariate results described above. When the dummy variable for
family firms with a single class of stock is omitted from the model, the dummy variable for
family firms enters with a negative coefficient that is significant at the 0.01 level. The
coefficient on the family firm dummy is –12.26 in the equation for lower level managers,
5 We thank Kevin Murphy for this suggestion.
19
indicating that the percent of total compensation accounted for by stock option grants is 12.26
percentage points lower in family versus control firms. The corresponding coefficient in the
equation for upper level managers is –9.69.
When the dummy variable for family firms with one class of common stock is included as an
independent variable, the dummy variable on family firms is no longer significant. The
coefficient on the dummy for family firms with one class of common stock is negative and
significant at the 0.05 level in the equation for lower level managers. This result indicates that
the low use of stock options in family firms is confined to family firms with only one class of
common stock. In the equation for upper level managers, the dummy variable for family firms
with one class of common stock enters with a negative coefficient that is not significant.
Cash bonuses
Since family firms rely less on both hierarchical incentives and stock option-based
compensation, it is worthwhile to consider whether these firms substitute other types of incentive
mechanisms for non-family senior managers, such as performance-based cash bonuses or
phantom stock. In the current version of this paper we examine whether sample firms are more
or less likely to use cash bonuses.
Table 3 shows that the median cash bonus paid to lower level managers in family firms is
$15,984, which is higher, but not significantly so, from the corresponding median of $10,352
paid to their counterparts in the control firms. Similar results hold for the mean value of this
variable. Qualitatively similar results also obtain when comparing the mean and median percent
of cash bonuses as a fraction of total compensation between the lower level managers of family
and control firms. The results suggest that family firms do not substitute a greater reliance on the
20
use of performance-based cash bonuses for dampened promotion incentives and less reliance on
executive stock options.
5. Conclusion
Family firms remain a predominant organizational form, yet little is known about the types of
incentive problems that exist in these firms, and how they are resolved. This paper attempts to
identify some incentive problems that arise in family firms when a child succeeds a parent as the
firm’s top manager. A controlling ownership stake held by the family, combined with the
relatively young age of the child at the time of succession, is likely to dull the promotion
incentives for other senior managers in these firms. This possibility leads to several testable
hypotheses about the level and structure of compensation of managers in family firms.
Our empirical results bear out some, but not all, of the predictions. Specifically, we find that
the difference in the compensation levels of upper versus lower managers is significantly smaller
in the sample of family firms. This result is consistent with the notion that incentives associated
with promotion to the highest position are significantly less important in family firms than they
are in other firms.
We find no evidence that family firms rely more heavily on incentive compensation as a
substitute for the dampened promotion incentives. Family firms award significantly fewer stock
option grants to their lower level managers than the control firms do, presumably because the
controlling families want to avoid dilution of their control. We find that dual classes of common
stock provide a mechanism for mitigating the aversion of family firms to use executive stock
options. Finally, family firms do not rely more heavily on performance-based cash bonuses than
other firms. In the next version of the paper, we will examine whether family firms use
phantom stock more heavily than other firms.
21
The ways in which family firms resolve their incentive problems remains puzzling, to a large
degree. One additional way in which family firms may resolve the dulling of promotion
incentives for senior managers is through more effective monitoring. Since the ownership
structure of family firms is highly concentrated among individuals actively engage in managing
the firm, the costs of monitoring the performance of low level managers is presumably lower
than might otherwise be the case. As a result, there may be less of a need, not only for
promotion incentives, but also for various forms of incentive compensation. We believe that this
is an area that also deserves attention in future research on this subject.
References
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Jensen, Michael C. and Murphy, Kevin J., 1990, Performance pay and top-managementincentives, Journal of Political Economy, 98, 225-264.
Lambert, Richard A., Larcker, David F. and Weigelt, Keith, 1993, The structure oforganizational incentives, Administrative Science Quarterly, 38, 438-461.
Lazear, Edward P. and Rosen, Sherwin, 1981, Rank order tournaments as optimum laborcontracts, Journal of Political Economy, 89, 841-864.
O’Reilly, Charles A., Main, Bran G. and Graef, Crystal S., 1988, CEO compensation astournament and social comparison: A tale of two theories, Administrative ScienceQuarterly, 33, 257-274.
Prendergast, Candice, 1999, The provision of incentives in firms, Journal of EconomicLiterature, 38, 7-63.
Rosen, S., 1986, Prizes and incentives in elimination tournaments, American Economic Review,701-715.
Smith, Clifford and Watts, Ross, 1992, The investment opportunity set and corporate financing,dividend, and compensation policies, Journal of Financial Economics, 32, 263-292.
Vancil, R., 1987, Passing the baton: Managing the process of CEO succession. Harvard BusinessSchool Press, Boston, MA.
Table 1
Sample of fam
ily firms and control firm
s, along with year in w
hich succession occurred in family firm
s, the age of the child in the year of succession, and the family
firm’s principal SIC
code and industry. Family firm
s were identified by searching the 4th quarter 1997 issues of Value Line for firm
s in which the chairm
an and eitherchief executive officer or president had the sam
e last name and the fam
ily owns at least 25%
of the firm’s stock. A
fter identifying these firms, w
e searched variousissues of M
oody’s Industrial and OTC M
anuals to identify the year in which the chief executive officer or president ascended to their position. W
e then searched proxystatem
ents for each family firm
to verify that a child had actually succeeded their parent as chief executive officer, president, of chairman of the board. The child’s age
also was recorded from
the proxy statements. The control firm
s were selected as firm
s in the same SIC
code (containing at least 10 firms) that w
ere closest to thefam
ily firm in m
arket value in the year of succession.
Year of
Age of child in
Family firm
Family succession year of sucession. Industry (SIC
) Control firm
Allied Products
Drexler
198235
Farm m
achinery and equipment (3523)
Toro Co.
Bandag
Carver
198234
Patent owners and lessors (6794)
Cum
mins Engine
Barnes G
roupB
arnes1995
46Steel springs (3493)
Acm
e Metals
Brow
n Forman
Brow
n1983
41D
ist. and blended liquor (2085)U
niversal FoodsC
ablevision Systems
Dolan
199540
Cable and pay TV
services. (4841)TC
A C
able TVC
omcast
Roberts
199030
Cable and pay TV
services. (4841)Tele-C
omm
TCI G
roupC
ulbroC
ullman
198438
Cigars (2121)
UST Inc.
Daniel Industries
Griffin
199147
Totalizing fluid meters (3824)
Dionex C
orp.D
illard. Dept. Stores
Dillard
197631
Departm
ent stores (5311)Jacobson Stores
Dollar G
eneralTurner
197737
Departm
ent stores (5311)A
mes D
ept. StoresEthyl
Gottw
ald1992
35Industrial organic chem
icals (2860)R
ohm&
Haas
Hechinger
Hechinger
198939
Lumber and building m
aterials retail (5211)G
rossmans Inc.
International Rectifier
Lidow1992
37Sem
iconductors (3674)V
ishay IntertechnologyK
imball International
Habig
198136
Wood office furniture (2521)
Tab ProductsLancaster C
olonyG
erlach1993
38Fruit, veget., sauces, seasonings (2035)
Seneca FoodsM
anor Care
Bainum
198640
Skilled nursing care fac. (8051)B
everly EnterprisesM
edia General
Bryan
199052
New
spaper publishing and printing (2711)A
.H. B
eloN
UI C
orp.K
ean1994
44N
atural gas distribution (4924)C
ascade Natural G
asN
ational Presto Ind.C
ohen1989
37Electric housew
ares and fans (3634)W
indmere D
urable Holdings
Nordstrom
Nordstrom
199532
Departm
ent stores (5311)Federated D
ept. StoresO
lstenO
lsten1990
37H
elp supply svcs. (7363)C
DI C
orp.O
wens &
Minor
Minor
198444
Med., dental, hosp. eqpm
ent – whsl. (5047)
Vallen C
orp.O
xford IndustriesLanier
197939
Mens, boys, w
ork clothing (2320)H
ampton Industries
Parker Drilling
Parker1991
42D
rilling oil & gas w
ells (1381)G
lobal Marine
Showboat
Houssels
199535
Coin-op am
usement devices (7993)
Aztar C
orp.Sm
ucker (J.M.)
Smucker
198036
Can fruit, veget., preserv., jam
, jel (2033)O
range Co.
Stand. Motor Prods.
Sills1986
47Electric eq. com
bust engin. (3694)Evans&
SutherlandSteel Technologies
Ray
199436
Cold roll steel sheet (3316)
Northw
estern Steel & W
ireTecum
seh ProductsH
errick1986
44M
easuring and dispensing pumps (3586)
Standex International Corp.
Wackenhut
Wackenhut
198639
Detect, guard, arm
or car service(7381)Executone Info System
sW
ashington PostG
raham1991
46N
ewspaper publishing &
print (2711)K
night Ridder
Werner Enterprises
Werner
199337
Trucking (4213)A
rnold Industries
Winn D
ixie StoresD
avis1982
37G
rocery stores (5411)Southland C
orp.W
olohan Lumber
Wolohan
198736
Lumber and bld. m
at. retl. (5211)R
iverside Group
Table 2
Summ
ary statistics on total assets, market to book ratio, and return on assets (R
OA
) for family and control firm
s. Total assets (in constant 1997 dollars) are defined asthe book value of assets, m
arket to book ratio as the ratio of the market value of assets (i.e., the sum
of the book value of debt and preferred stock plus the market value
of comm
on stock) to the book value of assets, and RO
A is defined as the ratio of operating incom
e to the book value of assets. All of the data used in these calculations
are taken from the C
ompustat tape. The data are averaged over all years, the years preceding the year of succession, and the years follow
ing the year of succession. Thesam
ple consists of 34 pairs of family and control firm
s. Thirty pairs have sufficient data on pre- and post-acquisition periods. The difference in medians is tested using
Rank-sum
z-test
Family firm
Control firm
Family firm
Control firm
Variable m
ean mean t-statistic m
edian median z-statistic
Total assets ($m)
All years
7091235
1.05305
275-0.18
All years (N
=30)786
13511.03
343374
0.16 Pre-succession
7411159
0.85281
3180.19
Post-succession838
15811.16
393377
-0.05
Market to book ratio
All years
1.1841.123
-0.491.063
1.004-0.70
All years (N
=30)1.250
1.172-0.58
1.0951.019
0.78 Pre-succession
1.2501.208
-0.311.149
1.0970.64
Post-succession1.256
1.142-0.82
1.1080.966
1.028
Return on assets
All years
0.06650.0686
0.260.0680
0.0610-0.40
All years (N
=30)0.0637
0.06670.35
0.06600.0615
0.16 Pre-succession
0.06800.0719
0.410.0690
0.0670-0.28
Post-succession0.0604
0.0583-0.22
0.06450.0520
0.73
Table 3
Summ
ary statistics for various compensation data for 34 pairs of fam
ily and control firms. A
ll compensation data are taken from
proxy statements and collected for the six years surrounding the year of
succession for the family firm
. Total compensation is com
puted as the sum of cash com
pensation (salary, bonus, and other cash compensation) and the value of stock option grants. Stock options are valued by
the Black-Scholes m
odel with continuously paid dividends. The stock price and com
pany dividend information, w
hich are used in the Black-Scholes valuation, are draw
n from the CR
SP and Com
pustat tapes.Estim
ates of the standard deviation of stock returns, also used in this calculation, are derived using stock return data for the year before the option grant. Interest rates on 10-year Treasury bonds are obtainedfrom
Federal Reserve B
oard statistical releases. All com
pensation data are presented in constant 1997 dollars using CPI discounts (obtained from
Missouri state w
eb server).
Variable
Family Firm
Control Firm
Family firm
Control firm
Mean M
ean t statistic median m
edian z-stat.
Total com
pensation Low
er managers
$452,519 $505,809
0.51$285,161
$386,156-0.75
Upper m
anagers 795,218
1,058,2631.06
548,468 796,456
-1.63 I
Percent differencein total com
pensationof upper versus
85.28115.09
1.64 70.98
86.051.71
*
lower m
anagers
Cash com
pensation Low
er managers
334,003316,356
-0.38280,635
282,934 0.44
Upper m
anagers562,993
670,383 1.02
474,122593,775
-0.79
Percent difference incash com
pensation ofupper versus
81.40107.85
2.05**
69.3595.25
-2.63***
lower m
anagers
Salary Low
er managers
241,343251,624
0.36211,746
238,630-0.30
Upper m
anagers408,845
508,2211.79
*382,215
501,919-1.34
Bonus
Lower m
anagers65,059
41,503-1.15
15,98410,352
0.99 U
pper managers
91,11388,294
-0.0818,000
12,7230.50
Other cash com
p. Low
er managers
27,60123,229
-0.314,434
1,6870.73
Upper m
anagers63,035
73,868-0.19
9,0702,198
1.20
Value of option grants
Lower m
anagers118,516
189,4531.00
20,519 64,621
-2.05**
Upper m
anagers232,225
387,8800.88
11,458138,363
-1.89*
Value of option grants
as % of total com
pensation Low
er managers
13.2625.32
2.60**
7.1022.47
-2.53**
Upper m
anagers12.44
24.462.28
*** 2.43
20.36-1.83
*
Bonus as %
of total compensation
Lower m
anagers13.03
7.25-1.65
5.70
2.401.50
Upper m
anagers12.53
8.12-1.07
3.161.96
1.19
***, **, *, Denotes significance at 1%
, 5%, and 10%
, respectively
Table 4
Summ
ary statistics for various compensation data, before and after a child succeeds his/her parent as president or chief executive officer of the com
pany. All com
pensation data are taken from proxy statem
ents and averaged over the threeyears before and three years after the year of succession. Total com
pensation is computed as the sum
of cash compensation, the value ofstock option grants, and other com
pensation listed in the proxy. Stock options are valued by the Black-
Scholes model w
ith continuously paid dividends. The stock price, company dividend inform
ation, and the interest rate on constant maturity ten-year Treasury bonds, w
hich are used in the Black-Scholes valuation, are draw
n from the C
RSP
tape. Estimates of the standard deviation of stock returns, also used in this calculation, are derived using stock return data for the year before the option grant. Interest rates on 10-year treasury bonds are obtained from
the Federal Reserve
Board statistical releases. All com
pensation data are presented in constant 1997 dollars using CPI discounts (obtained from
Missouri: state w
eb server).
Variable
Family Firm
Control Firm
Family firm
Control firm
Mean M
ean t statistic rank sum z m
edian median z-statistic
Total com
pensationLow
er managers
Pre-succession$491,212
$538,2830.34
$305,390$353,860
-0.57 Post-succession
413,958 477,294
0.75 298,445
390,350-0.51
Upper M
anagers Pre-succession
916,1351,075,153
0.46556,035
619,690-0.58
Post-succession674,019
1,093,4341.79
* 517,501
760,146-1.93
*
Percent differencein total com
pensation Pre-succession
93.14110.37
0.6682.12
88.55-0.41
Post-succession75.38
125.022.77 ***
61.01101.98
-2.41 **
Cash com
pensationLow
er managers
Pre-succession$332,106
$301,933-0.67
278,796266,248
0.57 Post-succession
338,957 330,054
-0.18290,781
298,793 0.30
Upper m
anagers Pre-succession
577,512608,732
0.35480,860
541,447-0.15
Post-succession549,556
727,9621.35
487,764585,506
-1.03
Percent difference incash com
pensation Pre-succession
90.54 98.28
0.5478.86
96.35-1.08
Post-succession72.45
112.912.75
***57.44
102.90-2.68
***
Value of option grants
Lower m
anagers Pre-succession
159,106236,349
0.66 6,282
42,714-1.53 I
Post-succession 75,001
147,2401.65
14,60272,198
-1.77*
Upper m
anagers Pre-succession
338,623466,420
0.425,886
27,289-1.02
Post-succession124,462
365,4722.01
** 319
120,803-1.80
*
Value of option grants
as % of total com
pensationLow
er managers
Pre-succession12.88
23.731.92
*2.61
18.72-1.62
Post-succession11.62
22.122.56
**4.68
20.87-2.23
**
Top managers
Pre-succession11.39
20.601.61
1.14 7.60
-0.91 Post-succession
10.7223.09
2.47 **
0.0616.30
-1.81*
***, **, *, Denotes significance at 1%
, 5%, and 10%
, respectively
Table 5A
Ordinary panel data least squares regressions of (i) the total com
pensation of top managers and (ii) the cash com
pensation of the top managers. Independent variables
include the average compensation of the low
er managers, the m
arket to book ratio, return on assets, and the two dum
my variables denoting fam
ily firms in the pre- and
post-succession years. T-statistics are in parentheses
Dependent V
ariable:Total C
ompensation
Dependent V
ariable:C
ash Com
pensationIndependent V
ariablesIntercept
195.89-25.25
81.23-42.28
(1.45)(-0.11)
(1.65) *(-0.43)
Average com
pensation of lower m
anagers1.86
1.811.89
1.65(19.07) ***
(16.32) ***(17.03) ***
(11.56) ***
Ln (Equity value)74.39
61.67(1.65)
(2.79) ***
Market to book ratio
-203.65-107.95
(-1.78) *(-2.22) **
Return on assets
1.08-1.69
(0.07)(-0.28)
Family dum
my
-161.07-107.66
-146.41-135.03
(-1.55)(-0.84)
(-3.33) ***(-2.50) **
Family post-succession dum
my
-103.81-31.03
(-0.72)(-0.51)
N346
346346
346A
dj. R-Square
0.52430.5264
0.46490.4752
Note:
Family dum
my plus
-211.47-166.06
Family post-succession dum
my
(-1.68) *(-3.17) ***
***, **, *, Denotes significance at 1%
, 5%, 10%
, respectively
Table 5B
Ordinary panel data least squares regressions of (i) the percent difference in the com
pensation of top managers and the com
pensation of lower m
anagers and (ii) the level of the topm
anagers’ compensation. The percent difference in the com
pensation of the top managers and the com
pensation of lower m
anagers is defined as the compensation of the top
manager m
inus the average compensation of low
er managers, divided by the average com
pensation of lower m
anagers. This percentage difference is computed for both total and
cash compensation. In regressions in w
hich these percentage differences are the dependent variable, the independent variables include the market value of the firm
(defined as thesum
of the book value of debt and preferred stock plus the market value of com
mon stock), the m
arket to book ratio (defined as the market value of the firm
divided by the bookvalue of its assets), return on assets (defined as operating incom
e divided by the book value of assets), a dumm
y variable that takes the value of one for family firm
s in the pre-succession years and zero otherw
ise, and a dumm
y variable that takes the value of one for family firm
s in the post-succession years and zero otherwise. T-statistics in parentheses.
Dependent V
ariable: Percent difference in totalcom
pensation for upper v. lower m
anagersD
ependent Variable: Percent difference in total
compensation for upper v. low
er managers
Independent Variable
Intercept143.56
127.36118.41
106.55(10.63) ***
(5.26) ***(13.50) ***
(6.19) ***
Ln(Equity Value)
0.492.89
(0.11)(0.93)
Market to book ratio
1.28-5.03
(0.11)(-0.58)
Return on assets
-2.31-2.40
-1.45-1.18
(-1.70) *(-1.58)
(-1.49)(-1.09)
Family dum
my
-26.45-15.87
-26.32-17.30
(-2.41) **(-1.17)
(-3.37) ***(-1.79) *
Family, post-succession dum
my
-20.51-17.42
(-1.35)(-1.61)
N346
346346
346A
dj. R-Square
0.01830.0151
0.03160.0328
Note:
Family dum
my plus
-36.38-34.73
Family, post-succession dum
my
(-2.76) ***(3.71) ***
***, **, *, Denotes significance at 1%
, 5%, 10%
, respectively
Table 6
Ordinary panel data least squares regressions of equity as percentage of total com
pensation. In regressions in which these percentages are the dependent variable, the independent
variables include the market value of the firm
(defined as the sum of the book value of debt and preferred stock plus the m
arket value of comm
on stock), the market to book ratio
(defined as the market value of the firm
divided by the book value of its assets), return on assets (defined as operating income divided by the book value of assets), free cash
flows/assets (m
easured as in Lehn and Poulsen, 1989) a dumm
y variable that takes the value of one for family, and a dum
my variable that takes value of one for com
panies with
single stock structure. T-statistics in parentheses.
Dependent V
ariable: equity/total compensation
*100 (lower m
anagers)D
ependent Variable: equity/total com
pensation*100 (upper m
anagers)Independent V
ariableIntercept
-6.97-2.36
0.003.38
0.261.84
(-1.55)(-0.54)
(0.00)(0.48)
(0.05)(0.38)
Ln(Equity Value)
3.203.46
3.232.96
3.163.00
(3.66) ***(4.11) ***
(3.84) ***(3.16) ***
(3.45) ***(3.27) ***
Market to book ratio
3.764.10
3.120.42
0.690.03
(1.68) *(1.91) *
(1.44)(0.18)
(0.29)(0.01)
Family dum
my
-12.26-3.49
-9.69-3.82
(-5.65) ***(-0.86)
(-4.10) ***(-0.85)
Family*single stock class
-10.41-6.97
(-2.53) **(-1.55)
N352
352352
352352
352A
dj. R-Square
0.06700.1429
0.15600.0309
0.07300.0767
Note:
Family dum
my plus
-13.90-10.79
Family*single stock class
(-6.18) ***(-4.38) ***
***,**,*,I denotes statistical significance on 1%, 5%
, 10%, respectively.