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Volumn 36, Issue 1, 2006, Pages 91-111

Learning to lose: Election outcomes, democratic experience and political protest potential

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EID: 29144470120     PISSN: 00071234     EISSN: 14692112     Source Type: Journal    
DOI: 10.1017/S0007123406000056     Document Type: Article
Times cited : (100)

References (83)
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    • M. Kent Jennings and Jan van Deth, eds (New York: de Gruyter)
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    • The International Social Survey Program (ISSP) is a continuing annual programme of surveys covering topics important to social science research (International Social Survey Program (ISSP), International Social Survey Program: Role of Government III, 1996 [Computer file] (Cologne, Germany: Zentralarchiv fuer Empirische Sozialforschung [producer]. Cologne, Germany: Zentralarchiv fuer Empirische Sozialforschung/Ann Arbor, Mich.: Inter-university Consortium for Political and Social Research [distributors]). The ISSP jointly develops modules dealing with important areas in the social sciences, fields the modules in a fifteen-minute supplement to the regular national surveys undertaken by the members, includes an extensive common core on background variables, and makes the data available to the social science community.
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    • note
    • For a variety of reasons, we excluded several countries from the ISSP dataset. For Cyprus and Israel, no fieldwork dates were available and it was impossible to determine which election the vote recall question referred to. For the Philippines, the variable measuring respondents' vote in the last election was missing. For France, the vote in last election variable measured only voter preferences in the first round of the last presidential election. For Poland it was unclear exactly which parties respondents voted for as response categories in the survey did not match choices available to voters. Finally, we excluded Bulgaria because political developments made it impossible to classify voters as being winners or losers. In that country, field work was conducted between February and May of 1997, but the government stepped down after protests in February of 1997 and was replaced by an interim government under the Mayor of Sofia until elections were held in April.
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    • Princeton, N.J.: Princeton University Press
    • Edward N. Muller, Aggressive Political Participation (Princeton, N.J.: Princeton University Press, 1979). See also Muller and Opp, 'Rational Choice and Rebellious Collective Action'. Because the repertoire of political action changed in the aftermath of the student movements of the 1960s and 1970s, the term 'unconventional participation' became less common as a description of various political acts outside of voting. Given that many of the acts that were considered unconventional have become conventional, we use the term 'protest potential' throughout this article.
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    • note
    • Following Muller and Opp ('Rational Choice and Rebellious Collective Action'), the composite participation potential variable is defined as the product of behaviour and intention, where behaviour is scored 1 for lack of participation and 2 for participation, and intention is scored 1 for negative intention, 2 for conditionally positive intention, and 3 for unconditionally positive intention. While this means that the dependent variable is weighted more towards measuring intentions than actual behaviour, note also that questions asking about actual anti-government activities may underestimate people's proclivities to engage in protest in new democracies because citizens in these countries are less accustomed to reporting anti-government activities. Thus, the 'would' component of the protest index may help capture some of the 'did' activities citizens are reluctant to report, and we believe that an index composed of 'would' and 'did' responses is superior to one constituted solely of one of them. Put another way, using only the "did" responses for our analysis is likely to lead to less valid inferences regarding protest behaviour. Overall, 16.7 per cent of respondents in our sample report having attended protest meetings, while 61.3 per cent indicated they would. Similarly, 14.3 per cent of respondents said they had attended protest demonstrations, while 48.9 per cent said they would do so.
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    • note
    • A constant equal to the number of items was subtracted from the total score in order to set the origin at zero.
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    • Errors in measuring vote choice in the national election studies, 1952-88
    • The measure of minority-majority status may suffer from the potential problem of biased recall or over-reports favouring the victorious party or in our case under-reports of having voted for the losers (cf. Gerald C. Wright, 'Errors in Measuring Vote Choice in the National Election Studies, 1952-88', American Journal of Political Science, 37 (1993), 291-316). This problem may be particularly acute because our surveys are not election surveys and the countries therefore had gaps of varying length between the last election and the conduct of the survey. As a check on the accuracy of the reported vote, we compared the aggregate distributions of actual election outcomes and recalled election outcomes. In our sample, 41.9 per cent of respondents reported voting for the losing parties in their countries; this is slightly higher than the 39. 3 per cent of actual citizens of voting age who voted for the losing parties. That is, over-reporting is actually slightly more pervasive than under-reporting at a magnitude of about 2.6 percentage points. While this could lead to misrepresenting the true effects of political minority status, such a distortion is likely to be minimal given the small differences between sample and actual population. Another source of bias could exist if voters who have a higher level of protest potential would over-(under-)report their vote for the losing parties. If such a bias exists, there should be a relationship between levels of protest potential and over-(under-)report of the vote for losers. We therefore calculated the difference between the reported and the actual vote in a country and correlated this figure (a measure of over-report or under-report of the losing vote) with the levels of protest potential. This correlation was statistically insignificant: Pearson's r= -0.2 (p = 0.4).
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    • note
    • Because not all surveys were conducted in 1996 (e.g., the New Zealand survey was conducted in 1997), countries' democratic histories varied between three years (Russia) and forty-seven years (New Zealand), with all the established democracies clustering at over forty years of democracy.
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    • note
    • There is a conceptual and empirical distinction between policy dissatisfaction with the current government and dissatisfaction because the voter's party did not get to form the government. Policy dissatisfaction is likely to be rooted in partisanship or ideology. Yet, while partisanship and ideology are long-standing predispositions that have their origins in early socialization experiences and have been shown to be quite stable during people's lifetimes, winning and losing vary as a function of how elections come out. Moreover, it is possible to be on the losing side of an election yet also have one's policy preferences implemented. To account for the impact of partisanship/ideology on protest potential in multivariate estimations, we included variables measuring people's left-right ideology and ideological extremism. Including these variables allows us to see whether being on the left or the right makes people more likely to protest (depending on who is in government). Moreover, given that governments (and governing coalitions) tend to be located near the median voter, we sought to estimate whether those outside the political mainstream - that is, those on the political extremes - are more likely to deny consent and try to bring about change or mobilize for it.
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    • We suspect that the satisfaction variable in part captures policy dissatisfaction as well.
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    • The ISSP surveys used here did not furnish variables measuring people's perceptions of economic performance. Thus, to the extent that economic perceptions deviate from objective reality, our estimates of the 'true' economic effects may be biased. To get a rough sense of how well objective economic conditions match up with economic evaluations, we constructed a dataset that included the West European countries included in our sample (comparable data were not available for the other countries). Using survey data drawn from the Eurobarometer and objective economic indicators for 1991-95, the Pearson correlation of growth and retrospective evaluations of national economy is robust and statistically significant: 0.68 (p < 0.01); the correlation of growth and retrospective evaluations of personal financial situation is similarly strong: 0.67 (p < 0.01).
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    • In part, this may be due to the correlations among the country-level indicators; for example, it is well established that democratic age and levels of freedom are correlated.
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    • In part, this may be due to the fact that the models that include the ideology variables are based on a smaller sample of countries, as Italy, Latvia and Spain are excluded from these estimations due to the non-availability of these variables for these countries.
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