explaining the salience of left-right ideology in postindustrial democracies. timothy hellwig
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Explaining the salience of leftright ideology in postindustrial
democracies: The role of structural economic change
TIMOTHY HELLWIG
Department of Political Science, University of Houston, USA
Abstract. Does leftright ideology structure electoral competition? While many studies
show that ideology is a powerful determinant of party choice, a growing number of scholars
claim that the salience of left and right has declined in recent decades. These contrastingviews motivate a consideration of whether the salience of the leftright dimension varies
across political parties and national contexts. Drawing on recent advances in the study of the
welfare state, this article argues that just as policy appeals expressed in the language of left
and right crystallised during a period of economic change, changes in the organisation of
postindustrial economies should weaken the leftright bases of competition. Analyses of 87
parties in 16 parliamentary democracies show that occupational heterogeneity in postindus-
trial economies indicated by employment in the private service sector and in industries
exposed to international competition reduces the salience of the leftright dimension for
the vote. The implications of study findings for future work on policy responsiveness and
electoral change in advanced capitalist democracies are discussed.
Introduction
To what extent does leftright ideology structure policy competition in
advanced industrial democracies? By assimilating the many issues that appear
before the electorate, the language of left and right provides parties andvoters with a shared policy space and students of politics with a powerful tool
for evaluating elitemass correspondence over policy. It should come as little
surprise, therefore, that studies of many electoral contexts find that leftright
ideology ranks as one of if not the largest determinants of party choice.
These findings appear inconsistent with research heralding a decline in
the salience of leftright orientations in many advanced industrial societies
(Inglehart 1990; Kitschelt 1994; Kitschelt & Rehm 2005; Kriesi 1998; Kriesi
et al. 2006; Manza & Brooks 1999). According to the latter perspective, the
utility of the leftright continuum for structuring competition in established
party systems has waned for some time, so much so that traditional socio-
economic cleavages now risk becoming secondary in importance to other
dimensions of policy contestation.
European Journal of Political Research 47: 687709, 2008 687doi: 10.1111/j.1475-6765.2008.00778.x
2008 The Author(s)
Journal compilation 2008 (European Consortium for Political Research)
Published by Blackwell Publishing Ltd., 9600 Garsington Road, Oxford, OX4 2DQ, UK and 350 Main Street, Malden,
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While it is commonplace to show that ideology in terms of left and right
influences the voters decision, no research has directly examined whether
the salience of the leftright dimension varies across political parties or elec-
toral contexts and, if so, whether this variance can be explained systemati-
cally. An understanding of the salience of leftright appeals, however, is
important for several reasons. First, a single encompassing dimension of
political contestation helps the voter sift through the many issues in election
campaign and select the party that comes closest to his or her own prefer-
ences. Second, thinking in terms of left and right provides a concise means
for elites to relate to one another. In this way, it serves as a coordinating
device for avoiding cyclical majorities. Perhaps most important, the existence
of a salient super-dimension is normatively appealing. To select parties on
substantive policy grounds rather than on less tangible factors like personalappeals requires that voters evaluate the policy positions of competing
elites in relation to each other. When parties become inseparable on policy
grounds, substantive political representation is likely to suffer as a result
(Pitkin 1987: 210213).
The purpose of this article is to examine the salience of left and right in
light of the now well-documented changes in advanced capitalist society.
My argument is that the salience of political ideology is a function of socio-
economic heterogeneity. Just as the socio-economic leftright divide solidi-fied in what were relatively homogeneous societies, so has leftright
ideologys salience declined as electorates have become more diverse. I iden-
tify two sources of heterogeneity: occupational change and dependence on
world markets. These factors increase the heterogeneity of the electorates
preferences and, in turn, diminish the utility of single-dimensional policy
voting. The argument is tested using representative sample surveys from 16
parliamentary democracies. Consistent with expectations, results demon-
strate that the salience of the leftright dimension is weaker for thoseemployed in services or in traded industries. Study findings carry implica-
tions for voting behaviour, party strategies and electoral change more
broadly.
The next section reviews the ways past research has measured and used
leftright ideology to understand political competition. Building on ideas that
new politics issues pose a challenge to the dominance of traditional policy
appeals, I then advance the claim that two structural factors deindustrialisa-
tion and globalisation may account for whether voter decisions continue to
be made in leftright terms. The fourth section reports results from an empiri-
cal analysis of recent national-level elections from 16 democracies. I conclude
with a discussion of study implications for future work on electoral change in
postindustrial societies.
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The salience of leftright ideology
The salience of political ideology for structuring political competition raises at
least three questions: How do we measure it; what does it mean; and how
important is it for the things we care about? Regarding the first question,
scholars have measured leftright placements using three principal means:
from surveys of party experts, from public opinion surveys and from party
manifestos. Internal validity checks and comparisons across data sources have
found these measures to do a satisfactory job of capturing policy-based politi-
cal competition, particularly in the developed democracies (Benoit & Laver
2006; Budge et al. 2001; Gabel & Huber 2000; Huber 1989; Huber & Inglehart
1995; Marks 2006; Warwick 2002).1 For empirical studies of representation, this
means that the leftright scale can be used as a kind of super issue dimensionto assess the preferences of citizens and policy makers. The leftright dimen-
sion also has been used to examine how party strategies affect vote outcomes
and in conjunction with other factors like partisan loyalties or performance
evaluations to judge the relative contribution of policy considerations to
party choice (e.g., Blais et al. 2004; Duch & Stevenson 2008; Lewis-Beck 1988:
84). In short, leftright ideology is widely shown to have a strong influence on
the voters decision.
Less attention has been given to the content of the leftright scale. Manyanalysts shy away from confronting the issue of content and instead leave it to
the individual respondent (either a respondent on a public opinion survey
or an expert tasked to judge party positions). Nearly all empirical studies,
however, conclude that party placements along the leftright scale are struc-
tured to a great extent by positions on state involvement in the economy.
Huber and Inglehart (1995) find that economic issues were cited as the most
important component of the leftright dimension in all but five of the 42
countries they examined. In a secondary analysis of Laver and Hunts (1992)expert judgments, Warwick (2002) shows that the leftright scale loads most
strongly on a set of economic issue items. And analyses of Markss and Steen-
bergens (1999) expert survey finds that their general leftright scale correlates
highly with an explicitly economic leftright scale (r= 0.92), indicating that the
two scales tap the same policy orientations for most parties. All told, evidence
from empirical investigations support Downs (1957) claim that party compe-
tition takes place along a leftright dimension based on disagreements over
the scope of government intervention in the economy.
Finally, researchers have been concerned with the third question about the
importance of left and right. A key question in comparative political
economy, for example, is whether and how government partisanship matters
for actual policy outcomes (e.g., Rueda 2005). This research programme
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assumes that party policy preferences can be assimilated onto a single left
right dimension. Likewise, studies of dyadic representation often employ left
right orientations to link citizens to elites (e.g., Miller et al. 1999). As Pierce
(1999: 30) puts it, the issue to which [voters] are likely to give high pri-
ority . . . is the ideological super-issue. . . . Voterparty congruence on more
specific issues, even those that are traditionally linked to the ideological
dimension, is much more limited.
The salience of leftright ideology, however, has been shown to be in
decline in Western democracies for some time. Some 25 years ago, for example,
only a third of French respondents agreed that ideas of right and left are
obsolete. By 2002, however, fully 60 per cent believed this to be the case (TNS
Sofres 2007). Instead of old socio-economic, class-based conflicts easily sum-
marised by left and right, scholars argue that an alternative dimension of policycompetition tapping non-economic, non-class-based concerns is growing
in salience. This alternative dimension has been variously termed post-
materialist-materialist (Inglehart 1990), libertarian-authoritarian (Flanagan
& Lee 2003; Kitschelt 1994; Kitschelt & Rehm 2005), green/alternative/
libertarian traditional/authoritarian/nationalism (Hooghe et al. 2002) and
integration-demarcation (Kriesi et al. 2006). As evinced by the various labels
employed, there is some disagreement over this second dimensions policy
content. Yet among its proponents, there is no disagreement that these issuesare distinct from the traditional socio-economic divisions associated with the
traditional leftright divide.
The emergence of a new set of issues carries several implications, including
the fortunes of class/mass political parties, the emergence of anti-system
parties, and, in general, the increase in electoral volatility and, possibly, elec-
toral dealignment. Have changes in electorates diminished the utility of the
leftright dimension as a coordinating device connecting voters to parties?
And if so, what explains variations in the salience of the leftright dimension?The next section advances the claim that the utility of a single super-dimension
for structuring party choice can be related to the diversity of the electorate
and, moreover, that this diversity can be attributed in part to structural change
in advanced capitalism.
Explaining the salience of the leftright dimension:
Socio-economic heterogeneity
Political parties may be conceived as group-based organisations charged with
maximising the utility of their constituencies. These constituencies have tradi-
tionally been characterised by inter-group differences in the direction of policy
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and by intra-group homogeneity over the salience (rank order) of policy
priorities. If the electorate is composed of two groups (e.g., the working class
and the middle class), delineated according to preferences in a single issue area
(e.g., concerns for redistribution), then a single leftright dimension provides
order to policy competition. However, if either the range of between-group
preferences over the direction of policy declines or the diversity of within-
group preferences over issue salience rises, then masselite congruence based
on a single dimension will weaken.
To illustrate, consider two ideal-type scenarios. In both cases, the parties
announce a set of coherent policy proposals known to all. In the first scenario,
all voters are assumed to have identical rankings in terms of the salience of
the issues. The only difference among citizens rests in the direction of their
positions. These directions define the parties constituencies. Here, the votersdecision problem simplifies to a task of identifying the party closest to his or
her preferred position on the most salient issue. All other issues are collapsed
into a dominant policy dimension or are discounted such that their effect on
the voters choice is indistinguishable from zero. In this scenario, a single
dimension works well for structuring electoral competition.The issue environ-
ment changes, however, when the salience of preferences within the party
constituencies becomes more diverse. Some voters may be concerned prima-
rily with issues of economic equality and economic efficiency, while others caremainly about issues that are not explicitly economic- or class-based, such as
health care or the environment. In this second scenario, this diversity of con-
siderations strains the capacity of parties and voters to communicate using a
single policy dimension.
A consideration of the role of voter heterogeneity coupled with a Down-
sian understanding that the content of the leftright dimension is dominated
by socio-economic/class-based concerns directs our attention on factors
expected to contribute to socio-economic heterogeneity. I identify two suchfactors: the expansion of the service sector and the exposure of national
economies to world markets.
Expansion of the service sector
The policies that emerged in the years following the Second World War were
a product of the conditions prevailing at the time a time in which economies
were organised for producing and competing in the manufacturing sector.
Industrialisation provided a vocabulary for mass politics as well. The working
class identified with positions on the left side of the continuum, while employ-
ers and capital owners identified with the right. These positions were linked
closely to policy-oriented parties. As Hibbs (1977: 1470) put it: Although the
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importance of socioeconomic status as a basis of electoral cleavage varies
substantially across party systems, the mass constituencies of political parties
in most advanced industrial democracies are distinguished. . . by class, income
and related socioeconomic characteristics. The implication was that party
issue positions could be readily arrayed along the traditional leftright spec-
trum. In this way, the economic leftright dimension crystallised in lock step
with the rise of industrial societies. Election outcomes were shaped by collec-
tive preferences for state involvement in industry and protecting the rights of
the industrial working class, on the one hand, and preferences for free markets
and limited government, on the other (Borre 2001).
In recent decades, however, economies have experienced large-scale struc-
tural change. While social classes have never acted as monolithic entities,
recent changes have made it particularly dubious to assume preference homo-geneity within class groups. Changes include the decline in union power,
decreasing employment in manufacturing, the growth of Post-Fordist produc-
tion technologies and the outsourcing of product inputs. A defining feature of
advanced capitalism, then, has been the decline of the industrial working class
and its replacement by the white-collar service sector.As Figure 1 shows (solid
line), the average share of workers employed in the private service sector
relative to the public and industrial sectors of the economy has grown steadily
over the past 30 years in OECD countries.2The effects of deindustrialisation range beyond the individual workers
material well-being. As Iversen (2005; see also Iversen & Cusack 2000; Iversen
& Wren 1998) argues, the size of the welfare state expanded as a kind of
compensation strategy to counteract the dislocating effects of service sector
employment. Via labour market deregulation and the curtailment of active
forms of employment protection, governments encouraged the growth of the
service economy as a strategy for coping with the constraints of otherwise
non-expansionary postindustrial economies. In this way, employment in theservice sector comprises a distinct welfare-production regime, separable from
regimes that rely on public sector employment or forms of social insurance as
forms of welfare compensation.3
In sum, if the leftright basis for political competition crystallised during
the period of industrialisation, its decline might be attributed to deindustriali-
sation.4 If true, then the leftright dimension should be less salient for voters
employed in the service sector of the economy relative to the electorate
overall. This brings us to our first testable hypothesis:
Hypothesis 1: Leftright ideology is less salient for voters employed in the
service sector of the economy than for those not employed in the service
sector.
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Economic globalisation
Along with occupational change, the growth of the international economy
ranks as the most fundamental change to domestic economies since thepostwar era. In 1970, the average level of trade (exports plus imports) as a
share of gross domestic product (GDP) averaged less than 50 per cent across
21 OECD countries. By 2000 this share was nearly 75 per cent (Figure 1,
dashed line). Exposure to the world economy may affect the salience of the
leftright dimension in two ways. First, like deindustrialisation, economic inte-
gration affects the heterogeneity of constituency preferences.As classic studies
by Gourevitch (1986) and Rogowski (1989) have shown, exposure to interna-
tional trade shapes political alignments within countries, creating tensions
between industry- and class-based coalitions. While domestic cleavages due to
preferences toward the international economy are not unique to postindustrial
economies, global markets affect larger shares of electorates now than at any
time in the past 60 years. Resulting tensions between left versus right and
30
32
34
36
38
40
42
44
1975 1980 1985 1990 1995 2000
Year
Percent
40
45
50
55
60
65
70
75
80
85
Private Services Employment,
% of Workforce
Trade as % of GDP
Figure 1. Employment in business services and trade openness: select countries, 19752002.
Notes: Services Employment (solid line, measured on the left-hand axis) is the number of
workers in the business service sector as a per cent of all workers for 13 OECD countries
(Australia, Canada, Denmark, Finland, France, Great Britain, Ireland, Netherlands, Norway,
Portugal, Spain, Sweden, and the United States).Trade Openness (dashed line, measured on
the right-hand axis) is measured as exports plus imports as a per cent of GDP for 21 OECD
countries (Australia, Austria, Belgium, Canada, Denmark, Finland, France, Germany, Great
Britain, Greece, Ireland, Italy, Japan, Netherlands, New Zealand, Norway, Portugal, Spain,Sweden, Switzerland, and the United States).
Sources: OECDs Industry Structural Analysis (STAN) database and World Banks World
Development Indicators.
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open versus closed makes the task of representation through political
parties more difficult. In open economies, parties must respond not only to
their constituencies in the domestic market, but also to the overlapping and
cross-cutting interests of capital and labour in the import-competing sectors of
the economy. This increases the chances that social cleavages will be cast in
terms of preferences for free trade versus protectionism rather than for or
against market regulation in general.
Globalisation might also affect the salience of the leftright dimension
through a separate channel: the policy capacity of national officials. The utility
of leftright policy voting or any sort of voting over policy, for that matter
should depend on the capacity of politicians to control policy levers. Rational
voters should make decisions based on preferences over the type and direction
of government action only if they believe that public intervention has thecapacity to affect citizen welfare. Dependence on global markets, however,
may compromise this capacity. If globalisation reduces parties ability to
pursue their preferred economic policy positions (in terms of lowering interest
rates or raising corporate taxes, for example) and if the public knows this to be
the case (as previous work indicates: Hellwig 2001; Hellwig et al. forthcoming),
then voters have little incentive to maximise utility in terms of leftright policy
congruence.5
This argument translates directly into a second expectation of how occu-pational alignments should affect policy voting: If opening up the economy
makes for more heterogeneous electorates, then the leftright dimension
should be less salient for voters employed in the exposed sector. This is our
second hypothesis:
Hypothesis 2: Leftright ideology is less salient for voters employed in
traded industries than for those not in industries exposed to competition
from abroad.
Analysis
In order to assess the influence of leftright ideology on the vote, I employ a
simple spatial model of voter utility. Spatial models express individual utility in
terms of the distance between the issue position of the party and the position
of the voter. This can be written in one dimension using a quadratic proximateutility model as:
U v p zij i j j i= ( ) + 2
, (1)
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where Uij is the utility of voter i for party j, vi is the ideal point of voter i on the
leftright dimension, pj is the corresponding position of party j and b is a
salience parameter greater than zero.The minus sign in front of the expression
denotes that utility is negatively related to the spatial distance between the
voter and the party. The vector dj represents the effect of non-policy consid-
erations zi on voter utility.
Using data from public opinion surveys, I estimate a statistical model for
multinomial choice where pij is the probability of individual i (i = 1, 2, . . . , n)
voting for party j(j= 1, 2, . . . , m).The model predicts that the probability that
i selects jis a function of the voters utility for jtaking into consideration his or
her utility for all other parties such that:
vote j
v p z
v p zi ij
i j j i
i k k i
=( ) = ( ) +
( ) +
exp
exp
2
2
=km
1
. (2)
Equation (2) can be estimated using conditional logit.6
Models akin to Equation (2) found in the literature generally assume that
all voters place the same weight, or salience, on elitemass policy congruence
(vi - pj). This assumption, however, may be inappropriate in some, if not most,
election contests, as work by Rivers (1988) and Glasgow (2001) suggests. Inorder to test research claims about the bases of leftright salience, I allow the
magnitude ofb to vary according to the voters occupational sector.According
to the research hypotheses, the utility gained for voter i from proximity to
party j on the leftright dimension should be less (in absolute magnitude) if i
is employed in the private service sector or in an import-competing industry.
These expectations pertaining to heterogeneity in the electorate can be incor-
porated into the model by interacting the leftright distance measure(vi - pj)2
with indicator variables for respondent occupation.
Data and measures
The empirical approach entails estimating party choice models using
individual-level data from 16 parliamentary democracies between 1999 and
2003. I use post-election surveys for Finland, Germany, Ireland, the Nether-
lands, New Zealand, Norway, Sweden and Switzerland provided by the second
module of the Comparative Study of Electoral Systems project (CSES 2006).
Due to missing or incomplete data on key variables, these studies are supple-
mented with data from the original national election studies surveys for Aus-
tralia (Bean et al. 2002), Denmark (Goul-Andersen et al. 2003) and Great
Britain (Sanders et al. 2002), and with data from the European Social Survey
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(ESS) for Austria, Belgium, France, Greece, and Italy (Jowell et al. 2003). I use
these data to estimate separate party choice models for each country.7
Models have the following variables in common. The dependent variable,
Party Choice, is coded with as many categories as there are parties standing
in the election. Those parties that lack measures on the leftright scale in the
survey or obtain less than 5 per cent of the vote are omitted from the analy-
sis, per standard conventions (e.g., Alvarez et al. 2000; Blais et al. 2004; Duch
& Stevenson 2008).8 For the election study surveys, the item asks for respon-
dent vote choice in the current election. For surveys from the ESS, respon-
dents are asked which party they voted for in their countrys most recent
national election. The Appendix lists elections and parties included in the
analysis.
The main explanatory variable, LeftRight Distance, is measured as thesquared distance between the voters position on the leftright scale, vi, and the
partys position, pj. For the voters position, I use the standard 11-point ques-
tion: In politics people sometimes talk of left and right. Where would you
place yourself on a scale from 0 to 10 where 0 means the left and 10 means the
right? For the CSES and election study surveys, the partys position is taken
from the mean of the respondents placement of the party on the identical
scale.9 For the ESS studies, I use leftright position as identified by experts
from Benoit and Laver (2006).10Finally, all country surveys include measures of respondent occupation.
For all studies, I make use of occupational codes from the International
Standard Classification of Occupations (ISCO-88).11 I use these data to clas-
sify respondents according to whether or not they are employed in the
service sector of the economy or in a traded sector of the economy. Codes
for service industry employment are informed by Iversen and Wren (1998)
and approximate those in Kitschelt and Rehm (2005). Respondents are
classified as belonging to the service sector if they identify themselves asclerks (ISCO-88 codes 411-422), service workers and market sales workers
(511-523), or sales and services elementary occupations (911-916). Following
Hays et al. (2005), I identify traded sectors using the OECDs Industry Struc-
tural Analysis (STAN) database. Respondents employed in traded industries
are those who identify themselves as skilled agricultural and fishery workers
(ISCO-88 codes 611-21), as craft and related trade workers (711-44), as plant
and machine operators and assemblers (811-34), or as working in elementary
occupations in agriculture, mining, manufacturing and transportation
(921-33).
In addition to measures for party choice, ideological distance and occupa-
tion, each country model includes a battery of individual-specific covariates as
informed by prior voting behaviour research.
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Results
Before reporting results across the 16 countries, I use the 2001 Danish Election
Study data to illustrate the analytic approach. The Danish party system
includes representatives from most major party families, making it an appro-
priate case for illustrative purposes. I begin with estimating the conditional
logit model. Model estimates are reported in Table 1. The dependent variable
is self-reported vote choice for one of the six largest parties in the Danish
Folketing (parliament). The second through fifth columns of the table report
the effects of individual-specific predictors on the vote, with the incumbent
Liberal Party (V) arbitrarily selected as the base category. Our primary inter-
est is with the first column, which reports results of the choice-specific policy
distance measure. As expected, the coefficient on LeftRight Distance is nega-tive and precisely estimated. This means that the greater the distance between
the voter and the party, the less likely the voter will be to select the party.
The magnitude of this effect, however, is contingent on occupational sector.
Coefficients on the two interaction terms, LeftRight Distance Service Sector
and LeftRight Distance Traded Industry are both in the expected positive
direction.
These results support the argument that leftright ideology is less salient
for voters who earn their income from the private services and traded sectorsof the Danish economy. Leftright placement, however, may be more critical
for some parties than others. Specifically, older mainstream parties such as the
Danish Social Democrats or Liberals have more invested in appealing to
class-based constituencies using a language of left and right than do parties less
than a decade old, like the Danish Peoples Party.12 However, since LeftRight
Distance is modeled as choice-specific, results reported in Table 1 do not allow
us examine the differences in the salience of political ideology across the party
choices (Train 2003). Post-estimation analyses are in order. I first obtain a setof predicted vote probabilities by drawing a vector of coefficients from a
distribution with mean equal to the vector of parameter estimates and vari-
ance estimated from the variance-covariance matrix. I then calculate the pre-
dicted probability that a hypothetical voter, i, selects party jusing the formula
for the conditional logit model (see Equation 2).13 In order to provide a
common benchmark for gauging leftright salience, for each party I set vi equal
to pj. This enables me to estimate the probability that i chooses j if is policy
preferences are identical to js position on the leftright scale.14
I perform this exercise three times corresponding to three occupational
profiles. Results are reported in Table 2. The first column of predicted prob-
abilities displays the probability that the voter selects the party when he or she
is employed neither in the service sector nor by an industry susceptible to
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Table 1. Conditional logit estimates of the 2001 Danish election. Dependent variable:
Respondent Vote Choice (Liberal Party coefficients normalized to zero)
SD/V DF/V KF/V SF/V RV/V
Choice-specific
LeftRight Distance
(LRD)
-0.232**
(0.018)
LRD Service Sector 0.137**
(0.023)
LRD Traded Industry 0.144**
(0.022)
Individual-specific
Service Sector 0.063 -0.056 0.194 -0.128 -0.080
(0.272) (0.339) (0.324) (0.451) (0.411)
Traded Industry 0.539* 0.993** 0.188 0.631 -0.366
(0.279) (0.308) (0.355) (0.466) (0.552)
Age 0.026** -0.012 0.039** 0.055** 0.040**
(0.009) (0.011) (0.011) (0.016) (0.014)
Female 0.086 -0.240 -0.407 0.321 0.082
(0.225) (0.278) (0.281) (0.366) (0.325)
Income -0.055 -0.153** -0.057 -0.113 0.027
(0.048) (0.053) (0.048) (0.079) (0.063)
Education 0.023 0.037 0.505** 0.673** 1.108**
(0.122) (0.151) (0.158) (0.217) (0.240)
Union 0.677** 0.695** -0.192 0.908 -0.312
(0.277) (0.320) (0.268) (0.586) (0.358)
Rural -0.193 -0.238 -0.411 -0.208 0.141
(0.220) (0.257) (0.291) (0.395) (0.347)
Constant -2.080** -0.244 -3.925** -6.694** -7.423**(0.781) (0.953) (0.935) (1.348) (1.246)
-2 log likelihood 2500.37
N 1,044
Note: Cells report conditional logit regression coefficients with standard errors in paren-
theses. The Liberal Party is the reference category for the individual-specific coefficients.
V = Liberals, SD = Social Democrats, DF = Danish Peoples Party, KF = Conservatives,
SF = Socialist Peoples Party, RV = Radical Liberals. ** p < 0.05, * p < 0.10, two-tailed test.Source: Data are from the 2001 Danish Election Study.
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Table2.The
effectsofservicesectorandt
radableindustryonleftrightpolicyvoting2001Danishelection
Partyjequa
ls
LeftR
ightposition
o
fpartyj
Probability
ofchoosingj
ifvoterisnotin
serviceor
tradedsector
Probabilityof
choosingj
ifvoter
isinservic
esector
Probabilityof
choosingj
ifvoterisintra
dedsector
SocialistPeoplesParty(SF)
2.8
0.26
0.13
0.18
SocialDemocraticParty(SD)
4.4
0.60
0.41
0.45
RadicalLib
erals(RV)
4.6
0.10
0.06
0.03
Conservativ
eParty(KF)
7.0
0.18
0.18
0.13
LiberalParty(V)
7.3
0.61
0.51
0.37
DanishPeoplesParty(DF)
8.1
0.21
0.16
0.33
Note:Calculationsperformedusingestima
tesreportedinTable1.Cells
reportpredictedvoteprobabilitiesforahypotheticalvoter
whoismale,
belongstoau
nion,doesnotresideinaruralarea,andhasmeanvaluesonage,educationandincome.Forallpartiesthevoterspositionplaced
attheidenticalpositionastheparty,suchthatvi=
pj.
Source:Data
arefrom
the2001DanishElectionStudy.
the salience of leftright ideology 699
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international competition. Here we see that if the voter places himself or
herself at the same location as the Social Democrats on the leftright scale (4.4
on the 010 scale), then he or she will vote for that party with probability of
0.60. Likewise, if the voter locates themselves further to the right, at 7.3, then
he or she will select the Liberals with a similarly high probability estimated at
0.61. Leftright placement has less of an effect on the remaining four parties,
as we might expect. More to the point, however, is that in all but two of 12 cells,
party vote probabilities decline when we change the voters occupational
status. For example, if the respondent is employed in the service sector, the
probability of selecting the Social Democrats falls from 0.60 to 0.41; if he or she
is employed in a traded industry, then the probability declines to 0.45.15
Having illustrated the statistical approach using the Danish data, Table 3
reports conditional logit estimates for all 16 countries. Model specificationsdiffer only in terms of the number of party choices (ranging from 3 to 7) and
in the selection of model controls. Given these differences, estimates for the
individual-specific covariates are omitted from Table 3 to facilitate presenta-
tion.16 Results show that in all cases, the coefficient on LeftRight Distance is
negative and estimated with high precision. Again, however, our main interest
pertains to voter heterogeneity due to occupation. Results across the cases
show that ideological congruence tends to be less important for voters in
positions in services and in industries exposed to international competitionthan for voters whose livelihood does not depend on these sectors. The coef-
ficient on the LeftRight Distance Service Sector interaction term is in the
expected positive direction in 12 of the 16 models and is statistically significant
in eight of these. Coefficients on LeftRight Distance Traded Industry also
are positively signed in 12 of the models, and nine of these estimates attain
acceptable levels of statistical significance. Equally impressive, in no instance is
an interactive coefficient large in magnitude and statistically significant with a
negative (unexpected) sign.And where results are weakest, this conforms withwhat we know about these political systems. Belgium and Italy are the only
cases where coefficients on both interaction terms are in the unexpected
negative direction, albeit with very large standard errors. Given the character-
istics of these democracies, these results should not be surprising. The Belgian
party system is structured based on linguistic cleavages as much as class-based
ones, and, given weak parties and high electoral volatility, we would not expect
strong findings for Italy.
Analysis of the Danish data showed the conditional effects of occupation
were greatest for the largest and oldest party on the centre-left, the Social
Democrats, and for the largest and oldest party on the centre-right, the Lib-
erals.To ascertain whether this finding generalises across the range of our cases
(i.e., that parties that have traditionally relied on leftright policy appeals have
700 timothy hellwig
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8/3/2019 Explaining the Salience of Left-right Ideology in Postindustrial Democracies. Timothy Hellwig
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Table3.The
effectsofservicesectorandt
radableindustryonleftrightpolicyvotingconditionallogitestimatesfor16countries
AU
2001
AT2002
BE1999
DK
2001
FI2003
FR
2002
DE2002
GB2001
LeftRightDistance
-0.085**
-0.097**
-0.047**
-0.232**
-0.137**
-0.121**
-0.122**
-0.191**
(0.007)
(0.008)
(0.006)
(0.018)
(0.014)
(0.012)
(0.009)
(0.016)
LRD
Serv
iceSector
0.027**
0.041**
-0.009
0.137**
0.052**
0.040**
0.056**
0.016
(0.013)
(0.017)
(0.016)
(0.023)
(0.020)
(0.020)
(0.014)
(0.030)
LRD
Trad
edIndustry
-0.005
0.016
-0.017
0.144**
0.039*
-0.004
0.057**
0.115**
(0.017)
(0.025)
(0.016)
(0.022)
(0.022)
(0.023)
(0.014)
(0.025)
-2loglikeli
hood
2314.27
2329.09
2202.59
2500.37
1988.69
1418.76
3857.24
2804.73
N
1,112
1,217
840
1,044
757
661
1,663
1,633
GR
2000
IE2002
IT2001
NL2002
NZ2002
NO
2001
SE2001
CH
2003
LeftRightDistance
-0.333**
-0.105**
-0.123**
-0.161**
-0.117**
-0.193**
-0.136**
-0.148**
(0.018)
(0.019)
(0.012)
(0.013)
(0.011)
(0.014)
(0.013)
(0.013)
LRD
Serv
iceSector
-0.135
0.045*
-0.023
-0.035
0.007
0.019
0.026
0.069**
(0.124)
(0.023)
(0.040)
(0.031)
(0.019)
(0.024)
(0.018)
(0.018)
LRD
Trad
edIndustry
0.070*
0.048**
-0.035
0.010
0.053**
0.061**
0.003
0.074**
(0.039)
(0.024)
(0.042)
(0.037)
(0.017)
(0.024)
(0.022)
(0.019)
-2loglikeli
hood
805.93
2663.44
1048.59
2274.74
1641.45
2713.23
1737.33
1632.31
N
1,208
1,102
506
829
715
1,023
1,044
783
Notes:Resultsreportonlythechoice-specificcoefficientswithstandarderrorsinparenthesesfromest
imatingak-choiceconditiona
llogitmodel
wherekisthenumberofmajorpartiescompetingintheelection.Resu
ltsoftheindividual-specificparametersareavailablefrom
theauthor.
**p