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First published online July 9, 2010

Dimensionality and the number of parties in legislative elections

Abstract

This article explores how the party-defined dimensionality of political competition relates to the number of parties competing in legislative elections. It demonstrates that a mathematical relationship between the number of electoral parties and the literature’s concept of dimensionality follows from the variables’ definitions; conversely, it argues that exploring the relationship between the number of electoral parties and a different concept of dimensionality conveys new information. Hence, it first argues that how we conceptualize dimensionality matters. Redirecting attention to the latter relationship, it then hypothesizes that party system fragmentation will go hand-in-hand with the appearance of new conflicts on the political agenda when the electoral system is permissive. Using a time-series cross-sectional dataset that includes at its core a new measure of dimensionality, it finds reasonable support for the hypotheses; however, at the elite level, new parties are found to play less of a role in politicizing new conflicts than expected.

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1.
Early versions of this article were presented at the 2006 Annual Meeting of the American Political Science Association, Philadelphia, PA, 31 August to 3 September and the 2006 National Conference of the Midwest Political Science Association, Chicago, IL, 20—23 April. An even earlier version can be found as parts of Chapters 4 and 5 of my dissertation. Thanks to Jim Adams; Michael McDonald; Benjamin Nyblade; Lorelei Moosbrugger; Jack Nagel; Tony McGann; Garrett Glasgow (in no particular order); and several anonymous referees for helpful comments on and/or discussions related to the article. All remaining errors of course remain my responsibility.
2.
1. To elaborate, parties may place conflicts that are salient within society on the political agenda (e.g. Cantillon, 2001); parties may seek to suppress conflicts that are salient within society by keeping them off of the political agenda (Cantillon, 2001); and parties may also seek to shape the set of societally relevant conflicts by putting conflicts not salient within society on the political agenda (Przeworski and Sprague, 1986). We note that conflicts salient within society are in turn likely to have roots in society’s exogenous or latent features such as its ethnic heterogeneity (Clark and Golder, 2006). However, relating these various spaces to one another is a topic beyond the scope of this article; see Stoll (2004) for some preliminary steps in this direction.
3.
2. This becomes even clearer when we take into account the conventional understanding of ‘political’ or ‘politicized’ in the electoral and party systems literature: that a political party breathes organizational life into the conflict (e.g. Bartolini and Mair, 1990).
4.
3. In fact, regarding its nomenclature, Lijphart’s earliest work (1981) used the term ‘ideological dimensions’. We can only speculate as to why he later (in 1984) switched to the less appropriate label of ‘issue dimensions’, which subsequent scholars then adopted.
5.
4. Laver and Hunt (1992: 23—4) term this version of the concept the ‘real’ dimensionality. We employ the label ‘raw’ instead of ‘real’ because the latter seems to imply that this definition of the concept is superior to others, an implication that we do not intend. Instead, we side with Collier and Alcock (1999: 539) in believing that ‘how scholars understand and operationalize a concept can and should depend on what they are going to do with it’.
6.
5. Alternatively, if his intent was to measure the raw dimensionality, the high association between the number of dimensions and the number of parties that he finds, in part a function of the prior coding decision, suggests that these measurements may have fallen victim to coding bias, that is, to the value of the dependent variable, the number of parties, influencing the coding of the independent variable, the dimensionality (Stoll, 2004).
7.
6. The CMP matches the quasi-sentences of each party’s manifesto for a particular election with a coding category of policy, such as ‘Free Enterprise’ and ‘Foreign Special Relationships: Positive’. The number of quasi-sentences in each category is then an indicator of the salience of that policy issue to the party. See Budge et al. (2001), and particularly the Appendix to the latter volume, for a detailed description of the project.
8.
7. Although this is ostensibly a measure of issue dimensionality, it is better viewed as a measure of ideological dimensionality, because the procedure just described simultaneously collapses issue into ideological dimensions, as we argued above in general terms.
9.
8. Let vi be the vote-share of the ith political party competing in an election. Then the effective number of electoral parties for that election is calculated as follows:■
10.
9. These scholars have not tested the direct linkage between the party-defined political agenda and new parties; rather, they have tested the indirect linkage between the voter-defined political agenda and new parties. Moreover, the measures of new societal issues have been indirect proxies such as the size of the population and ethnic heterogeneity.
11.
10. See, for example, Kitschelt’s (1997) work on the emergence of the authoritarian—libertarian dimension and the rise of radical right political parties in Western Europe. See also Meguid’s (2005) work on how the success of niche (green and radical right) parties depends upon mainstream parties’ responses to their entry, although we note that she black-boxes the question of entry (i.e. new party formation) itself.
12.
11. For example, Lipset and Marks (2000) argue that one of the reasons why third parties have failed in the United States is the electoral system, which impedes successful third-party entry. They argue that the other major reason is the institutional porousness of the Democratic and Republican parties, which leaves them vulnerable to internal takeovers. But see Chhibber and Kollman (2004) for an alternative institutional explanation.
13.
12. We calculate this statistic using Taagepera’s (1997) method of bounds. This procedure is designed to deal with small parties, which are commonly lumped together in one ‘other’ category by most election statistics.
14.
13. New parties are those that either result from a split in an existing party or are genuinely new; they do not include mergers and electoral alliances (see, for example, Tavits, 2006: 106). An alternative operationalization is simply the raw number of electoral parties, unweighted by vote-shares. However, we are unaware of existing time-series cross-sectional data on this variable (e.g. Tavits, 2006: 116).
15.
14. In earlier work, we developed several measures of what we have called the raw ideological dimensionality (Stoll, 2004). The measure introduced in this article makes only one minor change (which we believe is an improvement) to the most preferred of those measures, which we note leads to similar conclusions to those reported here. See the supplemental paper available from the author’s website for details regarding this and other models discussed but not presented in this article. We are unaware of other existing measures of the raw ideological dimensionality.
16.
15. See Stoll (2004) for a review of existing expert surveys as well as other data-generation procedures such as elite surveys. Unfortunately, large-N surveys have always focused on empirically identifying party positions along a common left—right dimension — not on quantitatively eliciting differences in dimensionality across either space or time. Leaving aside practicality, theoretical reasons for preferring the CMP to expert judgements are offered by Budge (2000). The most heated criticism of the CMP has focused on its use of issue salience to construct measures of parties’ positions (e.g. Laver and Garry, 2000), which is not how either we or Nyblade (2004) use it. Rather, we take the salience of issues in parties’ manifestos as an indicator of the salience of the issues to parties: salience is salience is salience, in other words. Other criticism of the CMP has focused upon its reliability (e.g. Mikhaylov et al., 2008). While we recognize this to be a concern, there is no available alternative source of data for us to use; moreover, to the extent that the CMP data are plagued by non-systematic measurement error, our findings will be biased downwards. Hence, we are stacking the deck against our hypotheses.
17.
16. Majoritarian electoral systems are those that use either plurality rule; absolute and qualified majority requirements; the alternative vote; or the single non-transferable vote (Golder, 2005). Of the countries in our analysis, Australia, Canada, France (except 1986), pre-1996 Japan, pre-1996 New Zealand, the United Kingdom and the United States employ majoritarian electoral systems using this definition. A well-known alternative operationalization is the logged average district magnitude (see, for example, Clark and Golder, 2006). The drawback to this operationalization is that it equates countries like Germany that have mixed-member proportional (i.e. permissive) electoral systems with countries like the United Kingdom that have plurality, single-member district (i.e. restrictive) electoral systems: both have average lower-tier district magnitudes of one. This strikes us as a significant disadvantage. Nevertheless, we note that using this measure instead of the simple dummy variable for majoritarianism yields similar conclusions about the hypotheses when the raw ideological dimensionality is employed, but less support when using the raw issue dimensionality.
18.
17. We do not include country fixed effects for consistency with the literature. However, including them yields generally similar results, with only H2 receiving less support. A random effects model is not used because our dataset is not clearly panel in structure, as per Beck and Katz (1996).
19.
18. In spite of their inclusion in the CMP, we — like Golder (2005) — exclude the Italian 1946 and Portuguese 1975 constituent assembly elections, as well as the sub-national Luxembourgian 1945—51 elections. We take data for the five CMP elections that do not appear in Golder (Canada 1945; Denmark 1945; Finland 1945; Norway 1945; and the United Kingdom 1945) from Stoll (2004). Note that we confine ourselves to the CMP’s advanced industrial democracies, that is, we exclude Turkey, out of a fear of comparing apples to oranges.
20.
19. Dropping either Belgium, Italy or Japan does not substantively alter the conclusions reported below. We drop the latter two countries because of the fragmenting of their party systems and the former because the CMP is based on an analysis of newspaper coverage of Japanese parties’ positions, not on their actual election manifestos. We thank Benjamin Nyblade for bringing the latter point to our attention.
21.
20. Allowing the number of new parties to serve as the dependent variable for consistency with the other models and using negative binomial regression yields substantively similar conclusions regarding H2 when using our measure of the raw ideological dimensionality, but less support when using Nyblade’s (2004) measure of raw issue dimensionality.
22.
21. Beck and Katz (1995) drew attention to the potential problem of cross-country contemporaneous correlations with political economy data. However, there are few electoral equivalents of global economic shocks, which suggests that this problem is not likely to surface in our dataset. Furthermore, even if we did worry about cross-country contemporaneous correlations, it would be difficult to obtain good estimates with few common time periods across countries and T << N.
23.
22. An alternative robust estimator, the country-clustered, yields less support for the hypotheses, particularly when using the measure of raw issue dimensionality from Nyblade (2004); however, the conclusions reported here remain substantively supported when using our measure of raw ideological dimensionality.
24.
23. Using the notation of these equations, the calculation is as follows: for permissive (non-majoritarian) electoral systems, the marginal effect is simply equal to β1; for restrictive (majoritarian) electoral systems, it is β1 + β3.

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Article first published online: July 9, 2010
Issue published: May 2011

Keywords

  1. electoral systems
  2. industrialized democracies
  3. new parties
  4. party fragmentation
  5. party systems

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Authors

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Heather Stoll
University of California, Santa Barbara, USA, [email protected]

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