Introduction

The popularity of far-right (sometimes also referred to as populist radical right)Footnote 1 parties across Europe has been rising rapidly in recent years. The latest political developments in Europe—such as the UK’s exit from the European Union—suggest that the surge of the far-right could have significant negative economic and political consequences for the entire continent. The rise of the far-right appears to be driven—in large part—by immigration. Since the early 1990s, Europe has experienced significant migration flows. First was the East to West migration from post-communist countries that began with the fall of the Soviet Union, and accelerated after the EU enlargements in the 2000s. Recent years saw a large inflow of asylum seekers from Asia and Africa fueled by a number of armed conflicts. Both of these immigration shocks likely kindled anti-immigrant sentiments across the continent, contributing to an unprecedented wave of electoral success among far-right parties.

This paper studies the effect of immigration on voting for the far-right on a local (municipality) level. This micro effect is facilitated through the personal contact between natives and immigrants as well as the perceived impact of foreign in-migration on local communities. By contrast, the macro effect of national immigrant inflows refers to the salience of migration in the national social and political discourse.Footnote 2 The micro-level impact of immigrants on natives’ voting choices is a priori ambiguousFootnote 3 and thus requires an empirical examination. This study focuses on Finland, a country that had a single far-right party (the Finns Party) for nearly 25 years (1995–2017) but was long considered immune to the surge of the far-right seen in other European countries (Ellinas 2010; Goodwin 2008; Ignazi 2003). The period of study is 2006 to 2015. These years are characterized by both the historically largest inflow of foreign citizens into Finland (Koivukangas 2003) and a remarkable rise in the Finns Party’s popularity. Indeed, there is a positive correlation between immigration and far-right voting on the national level (see Section 3 for more details). The analysis employs a novel panel dataset that spans 7 election years and 297 municipalities (all of mainland Finland). All types of national elections (i.e., parliamentary, presidential, and European parliamentary) are considered.

The sudden and unprecedented increase in immigration into Finland that followed the 2004 EU enlargement also provides an excellent setup for identification. The 2003 distributions of immigrants by continent of citizenship can be used to construct a “shift-share” instrument (Altonji and Card 1991; Orrenius and Zavodny 2015) to identify the effect of immigration on far-right voting. One thing that makes this instrument particularly convincing in this case is the change in immigrant composition that followed the 2004 enlargement. While the 1990s and early 2000s were characterized primarily by an influx of Ingrian Finns from the former Soviet Union and asylum seekers from countries such as Somalia and former Yugoslavia (Koivukangas 2003), the 2004 and the subsequent EU enlargements brought in mostly economic migrants from Central and Eastern Europe. This minimizes the concern that IV results could be driven by persistent trends in anti-immigrant or pro-immigrant attitudes across municipalities.

Using the shift-share instrument, I find an economically meaningful and statistically significant negative effect of municipal in-migration of foreigners on the Finns Party’s vote share. The IV coefficient from the preferred specification suggests that 1 percentage point increase in the share of foreign citizens in a municipality (68% of the mean) decreases the Finns Party’s vote share by about 3.35 percentage points (28% of the mean). Placebo tests using pre-period data confirm the IV estimate is not driven by persistent trends at the municipality level. To further validate the IV design, I re-estimate the main specification using a shift-share instrument constructed with 1991 immigrant distributions.Footnote 4 The resulting coefficient remains negative, statistically significant at 5%, and slightly larger in magnitude than the original estimate. Additional robustness checks such as the first-difference estimation, the inclusion of lagged-immigrant share, the exclusion of potential outliers, and the estimation with larger geographical units confirm the main result.

Considering the effect of immigration on voting for other parties, I find that the strongly pro-immigration Green League and Swedish People’s Party gain votes. Indeed, their positive coefficients roughly add up to the negative estimate for the Finns Party. These positive effects are also relatively large; a 1 percentage point increase in the foreign share increases the Green League’s vote share by 23% and the Swedish People’s Party’s vote share by 57% with respect to the sample means.

Exploring the potential mechanisms behind my main finding, I first show that local foreign in-migration increases voter turnout (3% with respect to mean), potentially activating a larger pro-immigration base. Interestingly, the share of protest votes remains unaffected by immigrant inflows. In addition, heterogeneity analysis reveals that the negative effect of immigration on the Finns Party’s vote share is only present in places with large initial exposure to immigrants. This finding provides some evidence in favor of Allport (1954)’s intergroup contact theory which suggests that a meaningful contact between natives and immigrants can effectively ameliorate natives’ anti-immigrant attitudes. Finally, I also find some evidence consistent with the welfare-state channel. In particular, I show that immigration increases municipal per capita personal income tax revenue, while per capita spending on social services, health care services, and education remain unaffected (Facchini and Mayda 2012; 2009; Dustmann and Preston 2007).

My analysis contributes to the growing economics literature on the effects of immigration on voting for the far-right and other anti-immigrant parties in Europe (described in more detail in Section 2).Footnote 5 Most studies find a positive effect (Halla et al. 2017; Barone et al. 2016; Becker and Fetzer 2016; Edo et al. 2019; Gerdes and Wadensjö 2008; Harmon 2018; Mendez and Cutillas 2014; Otto and Steinhardt 2014; Brunner and Kuhn 2018), while the negative relationship has only been documented in Steinmayr (2018), and to some extent also in Dustmann et al. (2019) and Levi et al. (2020).

This study is the first to show that an inflow of economic migrants can reduce support for the far-right across all types of national elections. By contrast, both Steinmayr (2018) and Dustmann et al. (2019) consider the exposure to refugees through refugee allocation schemes. In addition, Steinmayr (2018) evaluates the impact of a specific and relatively short-term event—the European refugee crisis—and considers only the extensive margin of immigration. This paper, on the other hand, focuses on the intensive margin and the study period spans 10 years and involves three types of national elections. Regarding Dustmann et al. (2019), the negative effect is present only in a limited subsample analysis of the 5% most urban Danish municipalities (i.e., 26 observations). By contrast, I find no effect heterogeneity with respect to initial population size—the negative effect is present in municipalities both above and below the median initial population size.

Second, this paper examines a broad set of electoral outcomes in a parliamentary democratic system, which before the emergence of the Finns Party was characterized by basic electoral stability and the implosion of the party system. The former refers to low volatility of electoral gains and losses while the latter describes a scenario in which all major parties become center parties capable of forming a coalition government with one another (Arter 2008). In this political setting, uniquely positioned to face the threat of a right-wing populist party, I consider the impact of immigration on voting for other parties and voter turnout, as well as the protest vote. A few previous studies have considered the impact of immigration on voter turnout. Barone et al. (2016) find a negative effect, while Steinmayr (2018) finds no effect. Dustmann et al. (2019) find a positive effect but only in municipal elections, whereas I find an increase in turnout in the context of national elections. As far as the protest vote is concerned, the only other paper that considers it is Barone et al. (2016). While they find an increase in the share of invalid ballots in response to immigrant inflow, I find no effect on the protest vote.

Third, Finland provides a unique setting in a number of other dimensions as well. Before the 2004 EU enlargement, Finland was a country with minimal immigrant inflow and a very low far-right popularity. Even after 2004, both the stock and the inflow of migrants remained relatively low compared to other EU countries (Eurostat 2020). In addition, the majority of immigrants have been from Europe, with a large number of economic migrants arriving from Central and Eastern Europe following the 2006 and 2007 labor market openings. Last but not least, Finland is also interesting as it is characterized by an extensive welfare state, highly educated and aging population, compressed wage distribution, and high union density, all of which have likely played an important role in shaping natives’ attitudes towards immigration (Sarvimäki 2011; Koivukangas 2003).

Fourth, this paper is one of only a handful of studies providing evidence for the welfare-state channel as a possible mechanism through which immigration affects far-right voting. This is particularly appealing given that Finland is a country with a generous welfare system (managed primarily by municipalities), and thus, native concerns about immigrant “benefit tourism” are especially relevant in this context. Previous papers have focused mostly on labor market and compositional amenities (Halla et al. 2017; Barone et al. 2016; Becker and Fetzer 2016), cultural diversity (Barone et al. 2016), the intergroup contact theory (Steinmayr 2018), and other non-economic aspects (Otto and Steinhardt 2014). Otto and Steinhardt (2014) do consider welfare channel as well, but they provide only indirect evidence.

The paper is organized as follows: Section 2 surveys the findings in the previous literature. Section 3 discusses the background. In Section 4, I describe the data and identification strategy. Results are presented in Section 5. Section 6 discusses potential mechanisms. Section 7 concludes.

Related literature

Far-right parties across Europe have strong anti-immigration rhetoric at the core of their political platforms. This feature stems from their ideology of ethno-nationalism (or nativism), defined by Betz (2008) to be a “strong belief that different societies and cultures adopt entirely different values, which are neither inferior, nor superior, but essentially incompatible with each other.” This ideology makes far-right parties both nationalistic and xenophobic, and in recent years also Islamophobic (Mudde 2007). In a recent report, Esipova et al. (2015) suggest that Europeans are the most negative in the world towards immigration, with 52% preferring lower immigration levels in their countries. Thus, to better understand the recent rise in the far-right in Europe, it is instrumental to study the role immigration plays in this process.

A growing number of recent papers in economics have explored this issue empirically, each focusing on a case of a specific European country. Halla et al. (2017) use a shift-share instrument to study the effect of immigrant inflow on voting for the Freedom Party of Austria (FPÖ). They find a positive effect which is driven by voters’ fear of the adverse impact of immigration on local labor markets and compositional amenities. In an Italian setting, Barone et al. (2016) show that foreign municipal in-migration increases vote share of the anti-immigrant center-right coalition (which includes the far-right Northern League). Proposed mechanisms in this study include cultural diversity, competition in the labor market and for public services, and political competition. Studies have also found a positive effect in Germany (Otto and Steinhardt 2014), UK (Becker and Fetzer 2016), France (Edo et al. 2019), Denmark (Gerdes and Wadensjö 2008; Harmon 2018), Spain (Mendez and Cutillas 2014), and Switzerland (Brunner and Kuhn 2018).

In contrast with the previous studies, Dustmann et al. (2019) use a quasi-random allocation of refugees into municipalities to study the impact of immigration on voting in Denmark. Documenting a large effect heterogeneity, the authors find that in all but the most urban municipalities, refugee inflow increases vote share of both anti-immigrant and center-right parties, while the vote share of center-left parties declines. However, in most urban municipalities, refugee allocation actually decreases support for anti-immigrant parties. The negative effect has also been documented in Steinmayr (2018) who suggests that hosting refugees in Austrian municipalities dampened the overall positive trend in support for the Freedom Party (FPÖ), consistent with Allport (1954)’s intergroup contact theory. Interestingly, he also finds that a brief exposure to a large number of refugees passing through the municipalities actually increased FPÖ’s vote share. Similarly, Levi et al. (2020), considering the dynamics of migration and the voting for Britain’s far-right UKIP, show that immigrants increase far-right support only in the short-run, while in the long-run, it is the opposite.

The relationship between immigration and far-right popularity is undeniably tied to the underlying attitudes of natives towards immigrants and immigration policy. Two economic channels have been identified as potential determinants of these sentiments. In line with the labor market hypothesis, Mayda (2006) finds that skilled individuals are more (less) likely to be pro-immigration in countries where the relative skill composition (i.e., ratio of skilled to unskilled labor) of natives to immigrants is high (low). Scheve and Slaughter (2001) draw a similar conclusion suggesting that less-skilled workers are significantly more likely to prefer limitation of immigrant inflows into the country.

The second economic mechanism is the so-called welfare-state channel. Consistent with its predictions, Facchini and Mayda (2012, 2009) find that in countries where immigrants are unskilled, pro-immigration preferences are negatively correlated with income and positively correlated with skill. These relationships are reversed in economies characterized by skilled migration. In a similar analysis, Dustmann and Preston (2007) find welfare concerns to be a more important determinant of natives’ attitudes towards immigrants than labor market concerns.

A number of studies have also emphasized the importance of non-economic mechanisms such as crime, xenophobia, and the cultural or national identities (Nunziata 2015; O’Rourke and Sinnott 2006; Mayda 2006), as well as the significance of social cohesion in general (Zimmermann 2019). In a cross-country analysis of OECD countries, Bauer et al. (2000) show that natives in countries receiving mostly refugees care primarily about social issues such as crime, while those in countries with a lot of economic migrants are more concerned about their labor market outcomes. Finally, immigrants can also affect natives’ non-pecuniary working conditions (Giuntella et al. 2019) and general life satisfaction (Akay et al. 2014, 2017). Both of these factors likely play an important role in determining natives’ sentiments as well.

Background

The Finns Party

The Finns Party (previously known as the True Finns; Finnish: Perussuomalaiset, PS) was the single far-right party in Finland since its establishment in 1995 until it split into two in mid-2017. In 1997, its first chairman, Raimo Vistbacka, was replaced by Timo Soini who led the party until 2017. Following a series of unsuccessful elections, the party made a breakthrough into the mainstream Finnish politics during the 2009 European election when it gained 9.79% of total votes (Fig. 1). In the 2015 parliamentary election, the Finns Party finished as a runner-up and for the first time formed a coalition government with the Centre Party and the National Coalition Party. Soini became the Minister of Foreign Affairs and the Deputy Prime Minister of Finland. In June 2017, following the election of new a chairman, Jussi Halla-aho, the party split into two: the Blue Reform remained in the coalition government while the Finns Party went into opposition.Footnote 6 My study period (2006–2015) ends 2 years before the split occurred. The following description applies to the period of the Finns Party’s uniform existence.

Fig. 1
figure 1

Finns Party’s vote share (all of Finland), 1996–2015. Notes - Data comes from Statistics Finland’s StatFin database

According to Norocel (2016), some Finnish scholars argue that the party is not necessarily a clear-cut case of far-right due to its strong left-leaning political agenda on economic matters. However, as Westinen (2014) points out, there is little doubt that the Finns Party is a nationalist-populist movement which combines ethno-nationalism and anti-elitism, typical features of far-right parties in Europe (Mudde 2007).Footnote 7 This view is shared by Arter (2010) who claims that the notion of true Finnishness (suomalaisuus) is the pre-eminent concept of the Finns Party’s ideology. Finally, Yla-Anttila and Yla-Anttila (2015) underline the points mentioned above suggesting that the Finns Party’s ideology combines a populist defense of a common man against corrupt elites, a defense of welfare state against market-led policies, and a nationalist defense of the sovereignty and unity of the Finnish people against immigration and federalist tendencies of the European Union. These points clearly suggest that the Finns Party can be considered a member of the European far-right family.

The party has a strong anti-immigration platform, as described in the following statement from its 2015 parliamentary election campaign pamphlet:

“Immigration will change, irreversibly, the host country’s population profile, disrupt social cohesion, overburden public services and economic resources, lead to the formation of ghettoes, promote religious radicalism and its consequences, and foster ethnic conflicts. [...] It can still be possible to avoid the immigration disasters of Sweden, France and the United Kingdom but it will require a determined policy and clear legislation.” (source: https://www.perussuomalaiset.fi/wp-content/uploads/2013/12/ps_immigration_final.pdf)

Moreover, according to the Chapel Hill Expert Survey (CHES) data, which describes policy and ideological positions of national political parties in the EU, the Finns Party has been the sole anti-immigrant party in Finland since 2006. As Table 1 suggests, throughout the study period, the party was consistently in favor of a tough immigration policy while strongly opposing multiculturalism (advocating for immigrant assimilation instead). In addition, immigration policy was a very salient topic in Finns Party’s manifestos (Table 1, column 4). Table 1 also reveals that none of the other main parties was anti-immigrant throughout the study period.

Table 1 Immigration position and salience - main political parties in Finland (2006-2014)

Other political parties in Finland

There are seven main political parties in Finland (other than the Finns Party): Social Democratic Party (SDP), Centre Party (Kesk), National Coalition Party (Kok), Green League (Vihr), Swedish People’s Party (SFP/RKP), Christian Democrats (KD), and Left Alliance (vas.). The first three (SDP, Kesk, Kok), each founded over a century ago, have traditionally been the strongest parties regularly placing on top of the electoral lists.Footnote 8 SDP is a moderate center-left social democratic party, while Kesk is centrist and Kok center-right, both of them having a liberal-conservative ideology (source: https://nsd.no/european_election_database/country/finland/parties.html). Although none of the seven parties was anti-immigrant during the study period, two of them—Green League and Swedish People’s Party—did have strong pro-immigration platforms. Indeed, as Table 1 shows, between 2006 and 2014, Vihr and SFP/RKP had low scores on both Immigration policy position and Multiculturalism, indicating an opposition to tough immigration policy as well as a preference for multiculturalism. Moreover, as with the Finns Party, Vihr and SFP/RKP both considered immigration policy to be a very important topic in political discourse (Table 1, column 4).

National elections in Finland

Parliamentary elections

Parliament of the Republic of Finland (Eduskunta) is unicameral, composed of 200 members directly elected by people for a 4-year term. Seats in the parliament are distributed among 13 electoral districts (or constituencies) in proportion to their populations 6 months prior to the election. This means that each constituency effectively holds its own parliamentary election. Candidates may be nominated by political parties or constituency associations (founded by at least 100 enfranchised persons from the same constituency). MPs are then chosen based on the number of votes they receive as well as the number of votes received by their party (or constituency association). Elections take place on the third Sunday in April, and voting can take place either in advance or on election day.Footnote 9 Eligible to vote are all Finnish citizens aged 18 or above regardless of their domicile (Ministry of Justice 2010).

Presidential elections

The President of the Republic of Finland is elected in a direct vote for a 6-year term. Each presidential candidate must be a native-born Finnish citizen, and no individual can stay in the office for more than 2 consecutive terms. Candidates are nominated by parties that have currently at least 1 seat in the parliament, or by constituency associations established by at least 20,000 people entitled to vote. The election proceeds in one or two rounds, the second round being essentially a runoff between the two most successful candidates from the first round. The second round takes place only if no candidate gains more than 50% of all votes in round 1. Each presidential election is held on the fourth Sunday of January (round 1), with the second round taking place two weeks later. Voting eligibility is the same as in parliamentary elections; advance voting is also allowed (Ministry of Justice 2010).

European elections

As a member of the European Union, Finland can elect Members of the European Parliament (MEPs) who serve 5-year terms. The number of Finnish MEPs is determined by the ratio of the Finnish population to the population of the whole EU.Footnote 10 Candidates for the European Parliament are nominated by political parties or constituency associations (established by at least 2,000 people), and voting proceeds as in the parliamentary elections. In contrast with parliamentary elections though, each candidate for an MEP enters the European election for the entire country. The election day is generally the second Sunday in June (Ministry of Justice 2010).Footnote 11

Immigration into Finland

Historically, Finland has been characterized by emigration (Sarvimäki 2011). From the end of World War II until the early 1970s, the country attracted very few migrants. Although immigration increased in the 1970s, throughout the 1970s and 1980s some 85% of immigrants were return migrants coming mostly from Sweden. A small number of refugees from Vietnam and Chile also arrived during this period (Triandafyllidou and Gropas 2008). It was not until the 1990s that Finland experienced a major inflow of foreign citizens (Koivukangas 2003). As Fig. 2 suggests, the first significant wave of foreigners began arriving in 1991 and was caused by the dissolution of the Soviet Union and the civil wars in the (former) Yugoslavia and Somalia. Ingrian Finns from Russia and Estonia and asylum seekers from Yugoslavia and Somalia made up the largest foreign immigrant groups in Finland throughout the 1990s (Koivukangas 2003). Due (in part) to a restrictive refugee policy,Footnote 12 the fraction of the population with foreign citizenship remained below 2% until 2003, one of the lowest in the EU during this period (Fig. 3; Koivukanga 2003).

Fig. 2
figure 2

Annual inflow of foreign citizens into Finland, 1990–2015. Notes - Data comes from Statistics Finland’s StatFin database. Total population is measured at the beginning of the calendar year

Fig. 3
figure 3

Share of foreign citizens in Finland, 1991–2015. Notes - Data comes from Statistics Finland’s StatFin database. Share of foreign citizens is measured at the beginning of the calendar year

As Fig. 2 depicts, the migration flow of foreign nationals into Finland increased dramatically in the late 2000s. In May 2004, the European Union accepted ten new member states (EU8 plus Malta and Cyprus).Footnote 13 This historic enlargement was followed by the accession of Bulgaria and Romania (January 2007), and later Croatia (July 2013). Due to fears of mass migration of workers induced by the large economic disparities between East and West, EU member states agreed upon the so-called transitional restrictions. These restrictions allowed each old member to postpone the opening of its labor market to the new members for a period of up to 7 years. Finland opened its labor market to Malta and Cyprus immediately in 2004 but chose to wait until May 2006 for all EU8 countries. For Bulgaria, Romania, and Croatia, the work-related immigration restrictions were lifted immediately upon their EU accession in January 2007 and July 2013, respectively (Pytliková 2014). Thus, while the 2004 enlargement already induced some inflow of foreigners (such as students) from Central and Eastern Europe, the two main immigration-inducing shocks were the 2006 and 2007 labor market openings. The period 2006 onwards is indeed the time of the largest immigrant inflow in Finnish history, and therefore, it is the focus of this study (see Fig. 2; Koivukangas 2003). As Fig. 4 confirms, the majority of incoming foreigners during this time were European citizens, primarily economic migrants from the new EU member states in Central and Eastern Europe (Fig. 5). Although, interestingly, the post-2006 period also saw a sizable increase in the inflow of non-European migrants (see Figures A.1 and A.2 in Appendix C, available in the https://www.econstor.eu/bitstream/10419/216900/1/GLO-DP-0540.pdf).

Fig. 4
figure 4

Immigration into Finland (by group), 1991–2015. Notes - Data comes from Statistics Finland’s StatFin database. Immigrants are divided according to their country of citizenship

Fig. 5
figure 5

European immigration into Finland (by group), 1991–2015. Notes - Data comes from Statistics Finland’s StatFin database. Immigrants are divided according to their country of citizenship

In the last couple of years, Finland has also witnessed a sizable inflow of asylum seekers from Northern Africa and Middle East. However, since the last national election in Finland took place in mid-2015, my study period ends at the onset of the recent European refugee crisis, before any significant number of asylum seekers arrived in Finland.

Data and empirical strategy

Data

The empirical analysis uses a municipality-by-election year panel dataset with 7 election years (2006–2015) and 297 municipalities. The following elections are used in the study: 2007, 2011, 2015 parliamentary elections; 2006, 2012 presidential elections (first round only); 2009, 2014 European elections. The Finns Party’s candidate in both presidential elections was its leader, Timo Soini, who was eliminated in the first round in both cases. Municipal elections are not used in the analysis since any foreigner with a permanent residency in a given municipality is eligible to vote in that municipality’s local election.Footnote 14 A similar concern arises with European elections since non-Finnish EU citizens with a municipality of residence in Finland are eligible to vote for Finnish MEPs (Ministry of Justice 2010). Figure 6 plots the distribution of the share of votes cast by non-Finnish EU citizens across all municipalities in the 2014 European election. The histogram shows that almost 35% of municipalities had no foreigners casting a vote.Footnote 15 Moreover, almost all municipalities are located below the 0.5% mark meaning the proportion of foreign votes cast in most cases was negligible. Histogram generated for the 2009 European election (available upon request) shows distribution that is even more skewed to the right. Nevertheless, as an additional robustness check, I exclude the 2009 and 2014 European elections from the analysis.

Fig. 6
figure 6

Distribution of share of votes by other EU citizens, 2014 European election. Notes - Data comes from Statistics Finland’s StatFin database

Spatially, the analysis extends to all of mainland Finland; excluded are only the Åland Islands (16 municipalities). Åland is a Swedish-speaking autonomous region that belongs to Finland and is located between continental Finland and Sweden. Its population makes up roughly 0.5% of the country’s total population (sources: Statistics Finland, Statistics and Research Åland). Although the region has its own parliament, the people of Åland also elect one member of the Finnish Parliament in every national parliamentary election. However, the Islands have their own political parties and so voting for the Finns Party is not an option. Moreover, since the region is not only linguistically but also culturally Swedish, it would not be appropriate to include these municipalities in the same analysis with the rest of the country.Footnote 16

In the past 12 years, the number of municipalities in Finland has been steadily shrinking to 313 (as of January 1, 2016). Municipality changes were mostly merges of two (or more) municipalities together. Information on all changes was provided by The Association of Finnish Local and Regional Authorities as well as Statistics Finland. The panel dataset is constructed using the 2016 municipality format. The dependent variable in the analysis is the Finns Party’s share of valid votes. The independent variable of interest is the share of foreign citizens in a municipality. The analysis also includes the following municipality-specific time-varying controls that likely affect voting for the Finns Party: log of total population, population density (per km2), share of females in adult population, share of population (aged 25–64) with tertiary education, share of aged 65+ in adult population, ratio of skilled to unskilled labor (in population aged 20–64), total crime rate (per 100,000 population), unemployment rate, and median household disposable income (per consumption unit). More details about the covariates are reported in Appendix A. All data comes from Statistics Finland’s public-use StatFin database. Table 2 provides the descriptive statistics for all variables.

Table 2 Descriptive statistics

A potential pitfall with using election vote share is naturalization, a process through which most foreigners without family ties to Finnish citizens obtain Finnish citizenship. Since naturalized Finns are de facto foreigners, a significant number of votes from these individuals will contaminate the dependent variable. However, as Gozdecka (2013) points out, Finnish citizenship has been a rather exclusive good aimed at foreign nationals who have put substantial effort into finding employment in Finland, learning Finnish language, and integrating themselves into Finnish society. This is indeed reflected in Finland’s naturalization rate,Footnote 17 which has had a fairly stable trend in the past 25 years (Fig. 7). During the 2006-2015 period, the naturalization rate had a declining trend (albeit with a considerable year-to-year variation). On average, the yearly rate was 3.6% during this time. Thus, although the problem with naturalization cannot be completely ruled out, the evidence presented here suggests that the number of naturalized Finns is not high enough to alter the results.

Fig. 7
figure 7

Naturalization rate in Finland, 1991-2015. Notes - Data comes from Statistics Finland’s StatFin database

Baseline fixed effects specification

The baseline empirical specification is the fixed effects model of the form:

$$ \text{Far-right}_{i,t} = \alpha + \upbeta \ \text{Foreign}_{i,t} + X_{i,t}^{\prime} \gamma + \lambda_{t} + \mu_{i} + \epsilon_{i,t} $$
(1)

where Far-righti,t is the Finns Party’s share of valid votes in municipality i and election year t. All elections used in the estimation take place in the first half of the year. The independent variable of interest, \(\text {Foreign}_{i,t} = \left (\frac {\# \text {of Foreign Citizens}_{i,t}}{\text {Population}_{i,2003}}\right )\), is the share of foreign citizens (as percentage of population in 2003) in municipality i and election year t. The foreign share is measured on the first day of the calendar year. As commonly done in immigration literature, I standardize the number of foreigners by the population in the base year of the IV (discussed later). Population at t is not used since it is likely endogenous to immigration. Xi,t represents the set of municipality-specific time-varying controls mentioned earlier. Since covariate values at time t are potential mechanisms through which immigration affects far-right vote share, I include them as 1 calendar year lags instead. The main specification also includes a full set of municipality fixed effects (μi) to capture municipality-specific time-invariant determinants of Finns Party’s vote share, and election year fixed effects (λt) to control for year-specific shocks that equally affect all municipalities (e.g., 2009 Eurozone sovereign debt crisis). Finally, the preferred specification also includes region-by-election year fixed effects to control for local business cycles and other year-specific shocks that affect equally all municipalities within the same administrative region. The fixed effects specification has been used extensively in the immigration literature (e.g., Orrenius and Zavodny (2015), Giuntella et al. (2019), Barone et al. (2016), Giuntella et al. (2018)). However, as a robustness check, I estimate an alternative first-difference model, following the strategy proposed by Sá (2014).

The OLS estimation of Eq. 1 will likely suffer from endogeneity issues arising from sorting among both natives and immigrants. First, immigrants may decide to avoid anti-immigrant far-right strongholds. This has been shown in a recent paper by Slotwinski and Stutzer (2019) to be the case in Switzerland after its anti-minaret referendum in 2009. Following the specification suggested in Halla et al. (2017), I directly test for this reverse causality by regressing the change in the 2006–2015 immigrant share on a number of initial conditions including the 2003 Finns Party vote share. Results of this OLS estimation are presented in Table 3. Reassuringly, the municipalities with significant initial far-right support do not appear to be receiving less migrants after the 2004 EU enlargement. However, even if immigrants do not sort based on the pre-existing anti-immigrant sentiments, they might decide to leave municipalities which turn hostile towards them. This reverse causality would bias OLS downwards.

Table 3 Direct test of immigrant sorting (OLS)

The second potential source of endogeneity is immigrant-induced native sorting. More specifically, an inflow of immigrants into a municipality may trigger an outflow of natives who face direct labor market competition (Borjas 2006). Also, as immigrants move in, natives who are anti-immigrant for non-economic reasons may decide to leave. A disproportionate number of natives who leave might therefore consist of far-right voters, in which case the OLS estimate will be biased downwards. On the other hand, pro-immigrant natives who derive positive utility from living in a diverse community could decide to move in together with the immigrants. Such inflow of natives who arguably do not support the Finns Party would bias the OLS estimate downwards as well.

Finally, as Borjas et al. (1996) suggest, immigrants may also cluster in areas with better socioeconomic conditions which are less supportive of the far-right, resulting in a downward bias as well. On the other hand, as Halla et al. (2017) point out, if a community is hit by a negative economic shock which depresses housing prices, it may actually attract immigrants. If this shock also shifts voters’ preferences to the far right, the resulting bias will be positive.

Identification

To identify the causal effect of interest, I employ an instrumental variable approach using a “shift-share” IV (Altonji and Card 1991). This instrument is based on an observation that immigrants tend to cluster in ethnic enclaves set up decades ago. My analysis uses a version of the instrument proposed by Orrenius and Zavodny (2015). More specifically, I first determine the distribution of foreigners by continent of citizenship across mainland Finnish municipalities in 2003 (base year). Then, for each of the election years in 2006–2015, the total nationalFootnote 18 counts of foreign citizens are distributed according to the 2003 distributions. The instrument has the form:

$$ \widehat{\text{Foreign}}_{i,t} = \frac{{\sum}_{j=1}^{6} \text{Foreign}_{t}^{j} * \text{Share in i}_{2003}^{j}}{\text{Population}_{i,2003}} $$
(2)

where \(\widehat {\text {Foreign}}_{i,t}\) is the predicted share of foreign citizens in municipality i in election year t, \(\text {Foreign}_{t}^{j}\) is the number of foreign citizens from continent j in mainland Finland in election year t, and \(\text {Share in i}_{2003}^{\ j}\) is the share of foreigners with continent of citizenship j in municipality i in 2003. As the summation indicates, immigrants are divided into 6 groups based on their citizenship (each group roughly corresponds to a continent): EU27 Europe,Footnote 19 non-EU Europe, Africa, Asia, America (North, Central, and South America combined), and Oceania. Figures A.3 and A.4 (in Appendix C available in the https://www.econstor.eu/bitstream/10419/216900/1/GLO-DP-0540.pdf) show the 2003 spatial distribution for each of these groups.

For the instrument to be valid, the predicted share of foreigners can affect the Finns Party vote share only through its direct effect on the actual share of foreigners. 2003 is chosen as the base year because it precedes the 2004 EU enlargement and the subsequent inflow of Central and Eastern European migrants. Moreover, it marks a change in the composition of immigrants coming into Finland (from asylum seekers to economic migrants). Thus, conditional on covariates and fixed effects, the 2003 distributions are unlikely to be correlated with unobservable predictors of anti-immigrant attitudes and Finns Party popularity after 2006. As an additional robustness check, the IV analysis is re-estimated using 1991 as the base year (15 years before my study period). Since immigration of foreigners into Finland was minimal before 1991, the results from this alternative IV estimation serve as further evidence validating the exclusion restriction of the original instrument.

The IV estimates could still be invalid if there is a persistence of municipality-specific trends in pro-immigrant and/or anti-immigrant attitudes. The inclusion of the region-by-election year fixed effects mitigates this concern. In addition, I conduct placebo tests with pre-period election data (1995–2003) to directly test for such persistence. Finally, if natives “vote with their feet” and if this native sorting after 2006 is correlated with the baseline immigrant distributions, IV estimate will be biased. I therefore re-estimate Eq. 1 using the same IV approach, but larger geographical units (administrative subregions and regions). A significant change in the IV coefficient will indicate the presence of such bias. In addition, I conduct a direct test of native sorting using an approach proposed in Peri and Sparber (2011).

Results

Main results

Before showing the regression estimates, it is useful to first consider visual evidence. In Fig. 8, I map the spatial distribution of Finns Party’s average 2006–2015 vote share as well as the distribution of the average 2006–2015 immigrant share. The figure suggests a negative relationship between immigration and far-right voting on a local level. In particular, the coastal municipalities in southern Finland (around the cities of Helsinki, Espoo, and Turku) have large immigrant shares but low support for the Finns Party. Similar pattern holds for a number of municipalities on the west-central coast (around the cities of Oulu, Kokkola, and Vaasa) as well as some municipalities in the northernmost region of Lapland. On the other hand, many of the landlocked municipalities in south-central Finland display a substantial support for the far-right party but a low concentration of immigrants.

Fig. 8
figure 8

Average Finns Party vote share vs. share of foreign citizens (2006–2015). Notes - Data comes from Statistics Finland’s StatFin database. 2016 municipality-level ArcGIS shapefile was provided by The Association of Finnish Local and Regional Authorities. Both maps depict all of mainland Finland (297 municipalities in total) and employ a Transverse Mercator projection. The 16 Swedish-speaking municipalities of Åland Islands are excluded

Table 4 presents main regression results from the estimation of Eq. 1 using OLS (cols. 1–3) and IV (cols. 4–6) methods. The coefficient of interest is negative and remains significant at 5% in all specifications. The OLS estimates are fairly small in magnitude (5–11% with respect to the sample mean). The IV coefficients are roughly 2–5 times larger than OLS depending on the specification. First-stage results (Table 12) confirm the instrument is strong; the Kleibergen-Paap rk Wald F-statistic (22.77) exceeds the Stock-Yogo 10% maximum IV size critical value even in the full specification (col. 3). The IV coefficient from the preferred specification (Table 4, col. 6) suggests that a 1 percentage point increase in the share of foreigners in a municipality (68% of the mean) decreases Finns Party’s electoral support by about 3.35 percentage points (28% of the mean). Put differently, 1 standard deviation increase in the foreign share decreases Finns Party’s vote share by 0.58 standard deviations. The large magnitude implies an economically important effect.

Table 4 Main results

For comparison, Steinmayr (2018) suggests that hosting refugees in a municipality decreases far-right FPÖ’s vote share by 4.42 percentage points. This magnitude is (in absolute terms) very similar to mine, although the two estimates are clearly not directly comparable since I consider the intensive margin of immigration. Dustmann et al. (2019) in their paper find that in the top 5% of urban Danish municipalities, 1 percentage point increase in the refugee share between electoral cycles decreases the vote share for anti-immigration parties by 3.79 percentage points in parliamentary elections. Given these parties’ overall vote share of 7.6%, this is indeed a similarly large effect. Lastly, Barone et al. (2016), finding a positive effect in Italy, show that 1 standard deviation increase in foreign share increases the vote share of the anti-immigrant center-right coalition (including the far-right Northern League) by 0.33 standard deviations. In relative terms, this effect is roughly half the size of my estimate.

The difference between my OLS and IV estimates is likely caused by attenuation bias arising from measurement error in the main independent variable. As Angrist and Pischke (2008) explain, if the measurement error is random, the OLS coefficient will be biased towards zero. An instrumental variable approach can correct for this bias. In the context of immigration, Aydemir and Borjas (2011) suggest that the attenuation bias arising from even a small measurement error can be significant if the model includes a large number of fixed effects. That is indeed the case here. Results in Sections 5.5 and 6.1 lend further credibility to the idea of attenuation bias. Using the same IV to estimate the effect of immigration on other electoral outcomes (e.g., voter turnout, other parties’ vote shares), I find that in every specification, the OLS estimate is attenuated towards zero, regardless of the coefficient sign (see Sections 5.5 and 6.1 for more details).

To explore the likely source of this attenuation bias, I consider more closely the procedure implemented by Statistics Finland to account for the foreign citizens living in a municipality in a given year. First, foreign citizens are counted in only if they intend to live in Finland for at least 12 months upon arrival into the country. Thus, some students, workers, and other visitors are excluded, even though their presence might affect natives’ voting preferences. Another important group that is not included in the measurement of the foreign population is asylum seekers whose applications are pending. On the other hand, foreign citizens with permanent residency in Finland are counted in the data even if they are temporarily living abroad, in which case my main independent variable will overcount the “true” immigrant population (Statistics Finland 2016).

Alternative first-difference specification

As the main robustness check, I estimate an alternative, first-difference version of Eq. 1 which uses net immigrant flow as the main independent variable. The specification is based on the main estimating equation in Sá (2014) and has the following form:

$$ {\Delta} \text{Far-right}_{i,t} = \upbeta \left( \frac{\Delta \text{ Foreign-born}_{i,t}} {\text{Population}_{i,2003}} \right)+ X_{i,t-1}^{\prime}\gamma + \lambda_{t} + \sigma_{i} + \epsilon_{i,t} $$
(3)

where ΔFar-righti,t is the level change in Finns Party’s vote share in municipality i between elections at t − 1 and t.Footnote 20ΔForeign-borni,t is the change in the number of foreign citizens in municipality i between t − 1 and t. To be consistent with Eq. 1, I standardize the change in the number of immigrants by population in the base year (2003). Covariates are included in lagged levels (Xi,t− 1) since the level changes between t − 1 and t are endogenous to immigration. Estimating a first-difference model means that the municipality-specific fixed effects are differenced out. Thus, σi captures municipality-specific trends in Finns Party’s vote share. Finally, λt captures national trends in factors that affect far-right vote share, such as the trend in Finland’s GDP per capita. To deal with endogeneity in β (the coefficient of interest), I construct the following instrument which uses the same distributions of immigrants by continent of citizenship in 2003 as the instrument in my main analysis:

$$ \frac{{\sum}_{j=1}^{6} \delta_{i, j, 2003} * {\Delta} \text{Foreign-born}_{j, t}}{\text{Population}_{i,2003}} $$
(4)

where δi,j,2003 is the share of immigrants with continent of citizenship j living in municipality i in 2003. ΔForeign-bornj,t is the change in the overall number of foreign citizens from continent j in mainland Finland between t − 1 and t. Estimation results are presented in Table 5. In columns (4)–(6), I replicate the analysis with population at t − 1 (instead of the population in 2003) in the denominator. Although the interpretation of β in the first-difference case differs from that in my main specification, reassuringly, all estimates in Table 5 remain negative and statistically significant at 5%.

Table 5 Alternative first-difference specification (IV results)

Robustness checks, placebo tests, and shift-share critique

I conduct a battery of additional robustness checks to test the sensitivity of the IV estimates. Results are reported in Appendix B. Table 13 confirms that eliminating some of the potentially “bad” controls (such as unemployment rate or median household income) does not significantly alter the results. In addition, using 1991 (instead of 2003) as the base year for the instrument slightly increases the magnitude of the IV estimates, although the standard errors increase as well due to a weaker first stage (Table 14). The IV estimates are also robust to the exclusion of European elections (Table 15) as well as the exclusion of 9 largest municipalities as potential outliers (Table 16). Although the full specification (column 3) in both Table 14 and Table 16 exhibit a weak instrument problem, the weak-IV robust Anderson-Rubin chi-sq. p-value confirms the 5% level significance of both IV estimates. Finally, I re-estimate the model separately for each election type (parliamentary, presidential, European). The coefficient on immigrant share is negative, statistically significant, and with comparable magnitudes across the three specifications suggesting that the negative effect is not limited to a specific type of national election (Table 17).

A natural concern with a shift-share instrument is that persistent trends at the municipality level may be correlated both with the IV and the outcome of interest. To partially address this endogeneity concern, I conduct a placebo test using pre-period election data. In particular, I estimate the following cross-sectional specification using OLS:

$$ {\Delta} \text{Far-right}_{i, 1999-2003} = \alpha + \upbeta \ {\Delta} \widehat{\text{Foreign}}_{i,2006-2015} + \phi_{r}+ \epsilon_{i} $$
(5)

where ΔFarrighti,1999 − 2003 is the level change (or percentage change) in Finns Party’s vote share in municipality i between 1999 and 2003, and \({\Delta } \widehat {{Foreign}}_{i, 2006-2015}\) is the level change (or percentage change) in the IV (using 2003 as baseline) in municipality i between 2006 and 2015. The regression also controls for region fixed effects (ϕr) and a set of municipality-specific controls measured in 2003. Results of the placebo test are presented in Table 6 (cols. 1 and 3). Reassuringly, a lack of any statistically significant correlation supports the validity of the IV’s exclusion restriction.

Table 6 Placebo test (OLS)

In columns (2) and (4) of Table 6, I repeat the same placebo analysis, but this time using the change in Centre Party’s vote share between 1995 and 1999 as my dependent variable. According to Jaakkola (2000), during this period, voting for the Centre Party was associated with negative attitudes towards immigrants. The Centre Party placed as a runner-up in both the 1995 and the 1999 parliamentary elections, capturing 19.9% and 22.4% of votes, respectively. Reassuringly, the results from this placebo test (Table 6, cols. 2 and 4) suggest no statistically significant correlation between the 2006 and 2015 trend in the shift-share instrument and the 1995–1999 trend in the Centre Party’s popularity, further strengthening the validity of my identification strategy.

The shift-share instrument itself has also been challenged in a recent paper by Jaeger et al. (2018), who argue that the estimate of the short-run effect of immigration could be “contaminated” by the long-run general equilibrium effect of previous immigrant wave(s). Thus, I follow their suggestion and include a 2-year lag of the share of foreign citizens in the main specification. Both the immigrant share and its lagged counterpart are instrumented for using the shift-share IV based on 2003 baseline distributions. Results are presented in Table 18. The main IV coefficient increases in magnitude while also remaining statistically significant at 0.1% level. Although the Kleibergen-Paap rk Wald F-stat. in the full specification (Table 18, col. 3) drops to 10.62, the weak instrument-robust Anderson-Rubin chi-sq. test confirms the statistical significance of the main estimate.

Direct test of native sorting

As noted earlier, another threat to identification comes from immigrant-induced native mobility. Different specifications have been suggested to test for it.Footnote 21Peri and Sparber (2011) evaluate each of these specifications using simulated data and find that some of them have built-in biases. They suggest estimating the following model which is based on Card (2009):

$$ \left( \frac{N_{i,t} - N_{i,t-1}}{\text{Pop}_{i,t-1}} \right) = \alpha + \upbeta \left( \frac{F_{i,t} - F_{i,t-1}}{\text{Pop}_{i,t-1}} \right) + \phi_{i} + \lambda_{t} + \epsilon_{i,t} $$
(6)

where Ni,t is the number of Finnish citizens in municipality i and election year t, and Ni,t− 1 is the number of Finnish citizens in i in t − 1 (i.e., 1 calendar year before t). Similarly, Fi,t and Fi,t− 1 refer to the number of foreign citizens in i at t and t − 1, respectively. Popi,t− 1 is the total population in municipality i in t − 1. The specification also controls for municipality fixed effects (ϕi) and election year fixed effects (λt). The coefficient of interest is β and its interpretation is as follows: β > 0 means there is an attraction between natives and immigrants, while β < 0 suggests a native outflow in response to the inflow of immigrants. Sá (2014) further points out that OLS estimation of Eq. 6 will likely lead to an upward bias in the estimate of β, since unobserved factors that attract immigrants into municipality could also attract natives. Therefore, I estimate (6) using the same shift-share instrument as before (with minor adjustments).Footnote 22 Equation 6 is estimated using both municipality-level and subregional-level data, where 67 subregions approximate local labor markets. Results (OLS and IV) are presented in Table 7. Neither of the four coefficients is statistically significant, suggesting that immigration did not induce native mobility.

Table 7 Direct test of native mobility

Another way to confirm that native sorting does not bias the main IV estimate is to re-estimate (1) using larger geographical units (subregions and regions). Mainland Finland consists of 18 administrative regions. The required underlying assumption states that if natives are mobile, they will sort within regions but not across regions (due to family ties and other costs of moving). Estimation results are shown in Table 19. All three estimates are negative and statistically significant at 1%. The regional-level coefficient is smaller in magnitude than its municipality-level counterpart, but the coefficients are not statistically different from one another. The subregional-level coefficient, if anything, is larger in magnitude than the municipality-level estimate. These findings mitigate the concern that native sorting and spillover effects confound my analysis.

Immigration and voting for other parties

An important aspect of any election study is understanding which parties benefit from one party’s loss of votes. In the context of my analysis, this means finding out which parties gained the votes Finns Party lost to immigration. Thus, I re-estimate (1) using vote share of every main party as the dependent variable (see Section 3.2 for further description of these parties).Footnote 23 Table 8 presents the results. As expected, the two parties that gained votes were the pro-immigration Green League and Swedish People’s Party. Their positive coefficients indeed add up to the size of the Finns Party’s negative coefficient. Moreover, the relative gains of these two parties were large, especially for the Swedish People’s Party (57% with respect to the sample mean).

Table 8 Immigration and election outcomes (all main parties)

Discussion of potential mechanisms

Immigration, voter turnout, and protest vote

In order to shed some light on the potential mechanisms through which immigration reduces Finns Party’s support, I first consider the impact of immigration on voter turnout (share of eligible voters who cast a ballot in an election) and protest vote (fraction of total ballots that are invalid). As Table 9 shows, foreign municipal in-migration increased voter turnout although the effect is small (3%). Protest vote was not affected. This suggests immigration induced natives’ participation in the election process, potentially activating anti-far-right voters who would otherwise not vote. It is also worth noting that the OLS counterparts to all coefficients in both Tables 8 and 9 are attenuated towards zero (see Tables 20 and 21 for comparison), further suggesting the presence of measurement error in the share of foreign citizens.

Table 9 Immigration and voter turnout, protest vote

Heterogeneity analysis and intergroup contact theory

Next, I test for the heterogeneity in the effect with respect to various initial conditions. In particular, first, the sample is split based on the median values of the following initial conditions: population, population density, immigrant share, Finns Party’s vote share, share of tertiary educated, skill ratio, median household income, and unemployment rate.Footnote 24 Then, separately for each initial condition, the share of foreign citizens is interacted with the above-median/below-median dummies. All regressions are estimated using the same IV as before. Results are reported in Table 10. The strong negative effect is present across municipalities regardless of their initial population size, density, level of education, skill ratio, median income, and unemployment rate. The coefficient is remarkably stable across different specifications both in terms of its magnitude and statistical significance. However, columns (3) and (4) do show some heterogeneity in the effect, since in both cases, the hypothesis that the two coefficients are equal can be rejected. Column (4) suggests that municipalities with higher pre-existing support for the far-right experienced a smaller reduction in anti-immigrant voting than the municipalities where Finns Party was less popular to begin with. However, the effect of immigration on high-nationalist municipalities is still negative and sizable, suggesting that the inflow of immigrants even into the far-right “strongholds” can ameliorate natives’ attitudes towards foreigners.

Table 10 Heterogeneity analysis (IV)

The most interesting result of Table 10 is presented in column (3). The negative effect of immigration on the Finns Party’s vote share is found only in municipalities with high pre-existing immigrant share. In other words, places where natives are already living side-by-side with immigrants are the ones that experience a reduction in anti-immigrant voting as a result of further immigrant inflow. This suggests that previous exposure to immigrants matters, providing some evidence in support of Allport (1954)’s intergroup contact theory. The importance of sustained contact between natives and immigrants is further strengthened by the results from an additional heteronegeity analysis, in which I split the sample by the 25th and 75th percentiles (Table 22). The negative effect is only present in the municipalities in the top quartile of the initial immigrant share (Table 22, col. 3). Interestingly, Table 22 also reveals that the effect is stronger in most rural places compared to the most urban communities (col. 2). However, given the weak first stage, this result has to be treated with caution.

Welfare-state channel

Last but not least, the welfare-state channel is yet another potential mechanism that could explain my main finding. There are two possible policy scenarios through which immigration affects the welfare system of the host country. On the one hand, migration can lead to changes in tax rates while per capita benefits are kept constant (tax adjustment model). On the other hand, tax rates might remain unchanged while per capita benefits adjust (benefit adjustment model). Under both scenarios, if immigrants are, on average, net contributors to the system (i.e., their tax contributions exceed the amount of social assistance they receive), both high-skilled and low-skilled natives will likely benefit from the presence of foreign workers due to a positive welfare spillover (Facchini and Mayda 2009, 2012). Therefore, an influx of such immigrants can ameliorate natives’ attitudes towards them, and thus make natives less supportive of the anti-immigrant Finns Party.

In the absence of any individual-level data on immigrant tax contributions and social assistance program take-up, I turn to municipality-level data instead. Using data from 2006–2010 (including non-election years), I consider the effect of immigration on municipal tax revenue and spending.Footnote 25 The analysis uses the same IV as the main estimation. I find a small positive effect of municipal in-migration of foreign citizens on per capita personal income tax revenue (2.5%), although the coefficient is statistically significant only at 10% (Table 11, column 2). On the other hand, there is clearly no effect of immigration on per capita property tax revenue or corporate tax revenue (Table 11, cols. 3 and 4).

Table 11 Immigration and municipality tax revenue and spending (2006–2010)

The provision of social welfare in Finland is delegated to individual municipalities (source: http://adapt.it/adapt-indice-a-z/wp-content/uploads/2014/08/ministry_finland_welfare.pdf). As Hytti and Paananen (2003) explain, immigrants with a resident permit valid for at least a year have the same rights to social security (i.e., unemployment benefits, family benefits linked to childbirth and child-rearing, and income support) as the native population. As Table 11, column (5) suggests, immigration had virtually no effect on municipal per capita spending on social and health care services. In addition, there was no effect of immigration on per capita spending on education and cultural activities. These findings suggest that an inflow of foreigners into a municipality did not overburden the provision of social welfare and other public services. Together with the positive effect on municipal income tax revenue, this suggests that welfare-state channel appears to be a plausible mechanism explaining the main finding.

Conclusion

This paper uses a novel panel dataset to study the effect of immigration on voting for the far-right Finns Party in Finland. Using an instrumental variable approach based on previous settlement patterns of immigrants, I show that municipal in-migration of foreign citizens has a statistically significant and sizable negative effect on Finns Party’s electoral support in national elections. In particular, a 1 percentage point increase in the share of foreign citizens in a municipality decreases Finns Party’s vote share by 3.5 percentage points (28% of the mean). This result—albeit consistent in magnitude with the negative estimates in Steinmayr (2018) and Dustmann et al. (2019)—runs contrary to most findings in the previous literature. Placebo tests using pre-period data suggest that the negative effect is not driven by persistent trends at the municipality level. The votes Finns Party loses due to immigration are captured by the two pro-immigration parties—the Green League and the Swedish People’s Party.

To explore the potential mechanisms driving my main finding, I first show that immigration increases local voter turnout, potentially activating a larger portion of the pro-immigration base in the municipality. In addition, heterogeneity analysis reveals that the negative effect of immigration on far-right popularity is present only in the communities with large initial immigrant share. This provides some evidence in support of Allport (1954)’s intergroup contact theory, which emphasizes the importance of sustained contact between natives and immigrants in ameliorating the local anti-immigrant sentiments. Finally, I provide some evidence consistent with the welfare-state channel as a potential mechanism. In particular, I find that foreign in-migration increases per capita municipal income tax revenue, while the per capita spending on social services, health care, and education remain unaffected.

Given the serious nature of the threat far-right parties pose to the European integration process, Europe’s security (with the ongoing threat from the Russian Federation), and potentially even the future of liberal democracy itself, the role of far-right parties in Western societies remains one of the most important topics of the public debate in Europe today. This paper contributes to the debate by presenting a unique case study showing that under some conditions, local immigrant inflow can actually reduce far-right popularity. To better understand the complexity of the relationship between immigration and far-right voting, future research needs to carefully address the interplay between the effects of micro-level and macro-level exposure to immigrants on far-right votes across the continent.