Urbanization and start-up rates in different geographies: Belgium, the Netherlands, and Sweden

Cities are often seen as entrepreneurial hotbeds (Van Oort and Atzema 2004; Fritsch and Mueller 2007; Bosma et al. 2008; Audretsch et al. 2015). Densely populated areas offer urbanization advantages which stimulate start-up activity. Moreover, entrepreneurial people are likely to reside in urban areas (Glaeser et al. 2010; Duranton 2014; Westlund et al. 2014). Cities do not function in a vacuum, however, and the benefits or disadvantages of a city may very well depend on the configuration of the settlement pattern it is in (Eliasson and Westlund 2013; Meijers and Burger 2015). Two similar cities, one a functional center in a mostly rural area, the other part of large conurbation, may have distinct start-up patterns as a result. Indeed, the empirical evidence on the role of urbanization in start-up patterns is ambiguous and some authors find that start-up rates are in fact higher in more sparsely populated rural areas (Fritsch and Falck 2007; Van Stel and Suddle 2008; Pettersson et al. 2010; Delfmann et al. 2014). In the Netherlands, there even appears to be a negative impact of urbanization on new firm formation (Van Stel and Suddle 2008; Delfmann et al. 2014). The mediating impact of settlement patterns on the role of urbanization in start-up patterns can provide an explanation for this.

The mediating effect of settlement patterns on start-up activity has two elements. Firstly, there can be country differences in the overall level of population density, i.e., the level of urbanization.¹ The overall level of urbanization is relevant as there is evidence that the effect of urbanization is not infinitely positive, and there are downsides to very high levels of urbanization (Bosma et al. 2008; Meijers et al. 2016). Frenken and Boschma (2007) suggest that a “ceiling” will be reached when the positive feedback processes are offset by negative feedback processes. In a scenario like this, a large city in a densely populated country can have lower start-up rates than surrounding regions, as these surrounding regions have a large enough population base to support positive urbanization economies without the negative effects of very high levels of urbanization found in the city. Indeed, for the Netherlands, it appears that urbanization disadvantages combined with increased possibilities for people to fulfill residential preferences outside cities, while retaining access to the urban centers, stimulates start-up activity in less-urbanized regions (Van Stel and Suddle 2008; Delfmann et al. 2014). A more technical way of seeing this is that the empirical relationship between start-up rates and urbanization can depend on the position in the overall distribution of urbanization and start-ups.

Secondly, access to cities can be an explaining factor of start-up patterns (Lavesson 2017). The concept of “borrowed size” (Alonso 1973) provides a useful explanation here. Originally applied to the situation where smaller cities borrow some of the urbanization benefits of their larger neighbors, it can be applied to rural-urban relationships as well. Access to the functions and networks of large cities can lead to higher average urbanization benefits in nearby areas, even though these functions are not present locally (Camagni et al. 2015; Meijers and Burger 2015; Meijers et al. 2016). As an illustration, Partridge et al. (2007) have shown that employment growth in rural areas is higher if the rural area is within daily commuting distance from an urban center. The same pattern may hold for start-up activity, and a rural region can experience relatively high start-up rates if it is located close to a major city. Yet, a relatively urbanized area in an otherwise distant peripheral region with weak connections to other major urban centers may have lower start-up rates than expected based on its urbanization level. Although access to cities is likely to be influenced by the overall level of density, it is also related to the urban settlement structure: some countries have one major urban area with a few smaller cities, while others have many cities of a similar size.

As of yet, there is no study known to us that explicitly considers the mediating role of national settlement patterns on the patterns of new firm formation. Given the ambiguous outcomes of different national studies, it is interesting to assess to what extent these differences can be explained by differences in settlement patterns. Therefore, the main goal of this study is to determine to what extent the relationship between urbanization and start-up activity differs depending on the settlement patterns present. The study considers the Netherlands, Sweden, and Belgium as these three countries offer distinct geographies and settlement structures in which potential differences should become visible. The OECD (2008) sees Belgium and the Netherlands as special cases in Europe with high urbanization rates and very dense population structures. Rural regions are always relatively close to urban regions in geographical terms. Sweden is a clear opposite in this respect. At the same time, the countries are relatively similar in their institutional environments (Koopmans 2010; Balcerzak and Pietrzak 2017).

The empirical analysis aims at identifying the influence of the geography of settlements of a country, in terms of access to cities and the level of urbanization, on the spatial patterns of start-up intensity.

To ensure a variation in the settlement patterns, the analyses focus on three European countries: Belgium, the Netherlands, and Sweden. These countries are interesting cases as they are quite similar in terms of institutions and culture³ (Koopmans 2010; Balcerzak and Pietrzak 2017), but they represent distinct national settlement patterns: the Netherlands and Belgium are among the most urbanized and densely populated countries of the OECD, while Sweden is a clear opposite. Performing the analysis for the three countries enables us to assess whether access to cities has a “generic” mediating effect or that it differs dependent on the geography of settlements in these countries.

The spatial patterns in start-up intensity are captured by the rate of new firm formation, which is the dependent variable in all analyses. The start-up rates are calculated using the labor market approach, and the potential municipal workforce is the denominator for standardizing the number of new firm formations (Audretsch and Fritsch 1994). To avoid yearly outliers, the mean start-up rates from 2008 to 2013 are used. The spatial unit of analysis is the municipality. This low level of aggregation is appropriate as new firm formation is a local phenomenon (Sternberg 2011; Audretsch et al. 2015). Indeed, most entrepreneurs start their business close to where they live (Figueiredo et al. 2002; Michelacci and Silva 2007; Stam 2009; Dahl and Sorenson 2012), and a sizeable share of all start-ups operate from home (Mason et al. 2011). Hence, it is plausible to assume that entrepreneurs are mostly influenced by local conditions. The analyses include all municipalities based on 2013 administrative divisions.

We adopt two regression models that are estimated with a maximum likelihood estimation (MLE). MLE provides a good alternative to estimation by ordinary least squares (OLS) which causes standard errors to be inconsistent for models including spatially lagged explanatory variables (Gibbons and Overman 2012). Alternatively, an instrumental variable (IV) approach could have been appropriate; however, the efficiency of these estimates depends crucially on the choice of the instruments (Anselin and Bera 1998). Hence, as the assumption of normality is met by the data, maximum likelihood is a logical choice. The first model relates start-up rates to the level of urbanization without controlling for settlement patterns and access to urban areas. The second adds controls for the settlement patterns. By analyzing the differences in the two models, it is possible to distill the mediating effect of the settlement patterns on the relationship between urbanization and start-up activity.

The control variables in the models account for alternative explanations for regional rates. We use the so-called eclectic theory as our frame of reference (Verheul et al. 2002). This approach says that regional start-up rates can be grouped into three broad categories: demand factors, supply factors, and institutions (see also Sternberg 2011). To avoid multicollinearity issues, we focus on the main factors in each broad category.

The demand side entails the opportunities for entrepreneurship created by the market demand for goods and services (Verheul et al. 2002). A key element in this is the industry structure, and we include the share of services as a control variable. A high degree of services is generally positively related to new firm formation due to the lower average start-up costs (Delfmann et al. 2014). Regional unemployment is also an important demand side variable though its impact is ambiguous, and it also affects the supply side of entrepreneurship (Verheul et al. 2002). A high unemployment rate may indicate a weak economy and therefore limited opportunities for entrepreneurship on the demand side. However, if unemployment is high, more persons may be driven into self-employment as job opportunities are scarce, raising the supply of entrepreneurs.

The supply side is further influenced by the characteristics of the population, i.e., the demographic composition (Verheul et al. 2002). One important demographic determinant for the regional level of new firm formation is the age distribution in a region. Cowling (2000) finds that in most European countries, entrepreneurs are between 41 to 45 years. In the Netherlands, entrepreneurs are slightly younger in average (36–40 years); while in Sweden, they are older (> 45 years). To capture this variation, the 35–50 age group is used as a reference category. Following Wagner and Sternberg (2004), we expect an inverted “U”-shape relation between age and the rate of new firm formation. Age is a proxy for personal wealth as older persons have had more time to accumulate wealth, which enables them to invest from their own resources. Also, young families with children may be reluctant to take on the risk of starting a new firm (Delfmann et al. 2014). This suggests a positive relationship between average age and start-up intensity. The positive effect may be offset by a negative effect with age as the career time to earn back sunk costs involved in starting a new business is relatively short for older ages. In addition to age, we control for the education level of the population and share of immigrants as both are found to be positively related to new firm formation (Armington and Acs 2002; Acs and Szerb 2007). Higher educated people generally have better resources to start a firm, and immigrants are on average less risk-averse, making them more inclined to start a business (Delfmann et al. 2014).

The institutional environment influences entrepreneurship mainly through the supply side as it influences individual attitudes toward entrepreneurship (Verheul et al. 2002). Most official institutions, such as bankruptcy laws and property rights, are similar in the three countries (Koopmans 2010; Balcerzak and Pietrzak 2017). We therefore focus on the “soft” side of the institutional environment—the entrepreneurial culture. These “soft” institutions are difficult to measure in practice (Aidis et al. 2012; Andersson and Koster 2011). Following Delfmann et al. (2014), we use the share of the public sector in a region as a proxy for entrepreneurial culture. A large governmental sector is assumed to negatively impact new firm formation (Nyström 2008; Aidis et al. 2012).

The three national statistics offices offer the data for the explanatory variables. For Belgium, the national statistics office also provides the data on the dependent variable new firm formations. For the Netherlands, start-up data is provided by the Chambers of Commerce that handles the registration of firm units. In Sweden, start-up data is provided by the Swedish Agency for Growth Policy Analysis. Although the data on start-ups come from different sources, the availability of general guidelines provided by Eurostat contributes to a harmonized and synchronized data collection in the European Union (Audretsch et al. 2015), ensuring relatively good comparability between different national data sources. Also, we study within country regional differences in start-up intensities and there is no prior indication that there is an important regional bias in the collection method across the countries. Relocations are excluded, but there is no distinction possible between new establishments of existing firms and genuinely new firms. Although motivations might be different for new subsidiaries or genuinely new firms (Van Oort and Stam 2009; Koster 2007), it is likely that both types of new firm formations are influenced by urbanization and urban proximity as these areas provide the largest consumer markets (Stam 2009; Bosma and Sternberg 2014; Audretsch et al. 2015). Also, Andersson et al. (2016) show that the composition of start-ups in terms of motivation for starting the firm—necessity vs. opportunity—does not vary markedly along the urban-rural hierarchy.

Table 1 provides summary statistics for the variables used. The statistics regarding start-up rates, population density, and the “distance to urban municipalities” are particularly relevant. The descriptive statistics illustrate the ambiguous relationship between density and start-ups. The Netherlands is the most densely populated country, and it has the highest average start-up rate. Belgium, however, despite its higher density, has a lower average start-up rate than Sweden. Demographic and economic differences may explain part of this, though the descriptive statistics show no clear differences. Hence, the Swedish population may be simply more entrepreneurial. Results from the Global Entrepreneurship Monitor (Kelley et al. 2016) also point to this, and perceived opportunities and capabilities of entrepreneurs are higher in Sweden than in Belgium while the fear of failure is lower.

In terms of access to urban centers, the Netherlands and Belgium are quite similar with Sweden being the clear outlier. In Sweden, the average distance from a municipality to the nearest urban municipality is much greater than in Belgium and the Netherlands. In fact, on average, the distance to the nearest urban municipality of any size is larger than the distance to the largest urban municipalities in the Netherlands or Belgium. There are also fewer small cities in Sweden, as indicated by the low values for the average incremental distance to the nearest urban municipality of at least 50,000 or 100,000 inhabitants. Although these average incremental distances are also low in the Netherlands and Belgium, this is caused by the fact that urban municipalities are located quite close to each other reflecting the high level of urbanization and the small sizes of the countries (OECD, 2008).

Figure 1 shows start-up rates by degree of urbanization for the municipalities in the three countries. Given the differences in geography between the north and the south of Sweden, they are indicated separately. As expected, the correlation between urbanization and start-up rates is positive (0.31). There are, however, interesting differences between the countries. For Sweden, the correlation is 0.44, which is the highest of the three countries. This correlation is even higher when only the south of Sweden is considered (0.60). For the Netherlands and Belgium, the correlation is much weaker, 0.26 and 0.11, respectively. The flatter distributions of these countries imply that there are relatively good opportunities for start-up activity in the whole country. It suggests that the settlement patterns shape the relation between urbanization and start-up patterns. Sweden and the Netherlands appear to occupy different positions in the same distribution, while Belgium has an on average much lower start-up rate given its regional density levels.

The bivariate positive relationship between density and start-up contrasts earlier findings for the Netherlands that indicated a negative effect (Van Stel and Suddle 2008; Delfmann et al. 2014). Clearly, the bivariate analysis needs to be extended to include possible confounding factors and selective sorting into urban areas. This may also account for the relative low start-up levels in Belgium. The figure also hints at the role of access to urban centers as mediating factors in explaining start-up rates. Particularly in the Netherlands, there are some clear outliers: some more intermediate municipalities have higher start-up rates than the most urbanized municipalities possibly resulting from easy access to larger urban areas. Such outliers are less clear in Sweden; although in the north of Sweden, there are some very sparsely populated municipalities that have relatively high start-up rates. This could suggest a positive “splendid isolation” effect as the regions are shielded from outside competition. Alternatively, there may be a measurement bias as municipalities in the north of Sweden are large in area, which cause them to have very low population densities, whereas the population lives concentrated in one part of the municipality. The effect of density may thus be understated. To account for this, we will perform an alternative version of the subsequent regression analyses in which the north of Sweden has been excluded (Section 8, Appendix IV).

Table 2 presents two models of start-up rates as a function of a series of explanatory variables for the three countries: the first model does not control for geography while the second model includes the spatially lagged urbanization variable and the distance to urban centers. This section first discusses the estimation results in general (model 1) and the differences between the countries before turning to the relative geography variables and how their inclusion influences the results (model 2).

The results of the first model indicate that in the Netherlands and Belgium, there is a negative effect of urbanization on start-up activity after controlling for other regional characteristics such as income and the share of higher educated people. The positive effect found in the bivariate analysis (Fig. 1) seems to be caused by selective sorting into cities and the economic characteristics of the cities as represented in the control variables. In the Swedish case, the effect of urbanization on start-up activity is not significant after controlling for additional municipal characteristics. This can be explained by the idea that particularly in Sweden, the geography influences the potential of spillovers. Compared to the most urbanized municipalities, start-up rates may be higher in more sparsely populated municipalities relatively close to the urban centers due to specific local characteristics in combination with positive urban spillovers. At the same time, sparsely populated municipalities located at a large distance from any urban center are likely to have lower start-up rates than the most urbanized municipalities. In the Netherlands and Belgium, these contradictory forces are likely to be much weaker, as most municipalities are located close to an urban center. After controlling for access to urban centers (model 2), the effect of own urbanization on start-up intensity should converge between the three countries.

The results for the control variables are mostly in line with previous findings. Only the inverted “U”-shaped relationship of age, as hypothesized by Wagner and Sternberg (2004), is not supported by our results. Moreover, the effect of age structure on start-up dynamics differs across the countries. In the Netherlands, regions with relatively large shares of the population outside the labor force (younger than 15 and older than 65) have relatively higher start-up intensities. This suggests that differences in demand structure may be driving this result rather than the supply of business owners. Alternatively, young families with children may be more inclined to start a business to benefit from the flexibility it offers (Delfmann et al. 2014). In Belgium, the effect of the share of 15–25- and 25–35-year-olds is significantly positive, implying that with respect to the share of 35–50-year-olds, municipalities with a younger population are more conducive for start-up activity. Moreover, whereas the effect of the share of 50–65-year-olds is significantly negative—though only weakly so—the effect of the share of the population aged over 65 is again significantly positive. In Sweden, and in line with Petterson et al. (2010), there is a positive effect of the 50–65-year-olds on start-up activity, as compared with the reference category. For the older ages, entrepreneurship can offer a form of partial retirement, as self-employment offers greater flexibility to accommodate tastes for leisure (Quinn 1980). Moreover, the increasing importance of Internet-based service firms operating from home, with relatively little start-up costs, allows one to earn back investment costs sooner (Colombo and Delmastro 2001), making starting a new firm a feasible career option for older people.

In the second model in Table 2, we enter the relative location of municipalities by including the distance to cities and the lagged urbanization variable. Importantly, the effect of population density—i.e., the level of urbanization—is now significant and negative for all countries and the effects of urbanization are of similar strength. This convergence is consistent with the idea that differences in settlement patterns mediate the effect of urbanization on start-up rates. As such, it provides a likely explanation for ambivalent results in earlier studies that did not explicitly address the relative geography in which cities are located (see, for example, Fritsch and Falck 2007; Bosma et al. 2008; Pettersson et al. 2010; Delfmann et al. 2014; Audretsch et al. 2015). It also suggests that, after controlling for regional characteristics and relative location, the three countries though at different levels are part of the same linear relationship between density and start-up patterns.

The effects of interaction between cities and surrounding regions differ across the three countries. In the Netherlands, the direct effect of the level of urbanization of the neighboring municipalities on start-up activity is negative, suggesting competition effects. Given the overall higher density in the Netherlands, the benefits of urban spillover stemming from density is relatively low and municipalities are more substitutes than complements. In Belgium however, which has a similar level of population density, there is no significant direct effect of the level of urbanization of neighboring municipalities on start-up activity. This might be explained by differences between Flanders and Wallonia: Flanders is similar to the Netherlands in terms of its urbanization level, and it is likely that competition effects are also important here; whereas in the less-urbanized Wallonia, regions can be more complementary. These two opposing forces cancel each other out if Belgium is considered as a whole. To correct for this, we have performed a robustness check in which Wallonia has been excluded, which will be discussed below (Section 8, Appendix III). In Sweden, a municipality is more conducive for start-up activity if positioned in a more densely populated wider region. Swedish start-ups are relatively often located in more urbanized regions, though not in the urban centers.

Distance to urban centers has a negative effect on start-up rates. Furthermore, there is an additional penalty for being removed from larger cities. A municipality does not have to be very densely populated itself to be conducive for start-up activity. Indeed, after controlling for other factors, the effect is negative. Being close to an urban center, preferably a larger one, is beneficial for start-up rates. The squared distance variables are generally positive, implying that there is a point where greater distance from an urban center insulates the municipality from urban competition—i.e., the “distance-protection” effect as noted by Polèse and Shearmur (2004).

Belgium is an outlier, and only the squared distance from the nearest urban center contributes to the explanation of municipal start-up rates. Only municipalities located very far from an urban center are less conducive for start-up activity. The insignificant effects of increasing distance from cities of other sizes can be explained by the fact that the small size of Belgium in combination with its high level of urbanization ensures that rural areas may never experience backwash from any urban center before they encounter positive urban spillovers from another (Partridge et al. 2007). However, for the Netherlands, also a small and highly urbanized country, all urban tiers have a significant effect. Differences in the perceptions of population can provide a tentative explanation for this: Belgians may be willing to travel further for work than Dutch people. In that case, urban spillovers also extend over a larger distance. The on-average longer commuting distances in Belgium compared to the Netherlands are in line with this explanation (Verhetsel et al. 2009; Statistics Netherlands 2016).

For Sweden, the distance to the nearest urban center and the incremental distance to the largest urban centers—i.e., those of 250,000 inhabitants or more—have significantly negative effects on start-up activity. This is likely caused by the fact that Sweden hosts fewer smaller urban areas than the Netherlands or Belgium. Often, the nearest urban center in Sweden has 50,000 or 100,000 inhabitants and therefore there is no additional distance penalty. In addition, in Sweden, there is also a “distance-protection” effect for the municipalities located very far from an urban center. Interestingly, this “distance-protection” effect kicks in at a much larger distance in Sweden than in the Netherlands. For example, in the Netherlands, the squared term for distance to the nearest urban center indicates that around the hypothetical distance of 40 km from an urban center the distance effect becomes positive; whereas for Sweden, this “distance-protection” effect only starts at about 200 km. Differences in perceptions can again be the key here. What is considered as a long trip in the Netherlands may be less problematic in the Swedish context (Delfmann and Koster 2013; Sandow 2008; Statistics Netherlands 2016).

We tested the robustness of the results in several ways. As it can be argued that the cut-off point for the spatial weights matrix used to calculate the spatially lagged urbanization variable is to some extent arbitrary, we reran the regression analyses using spatial lags based on cut-off points of 30, 70, and 100 km. We also performed analyses where we excluded the incremental distances to cities of over 50,000 and over 100,000 inhabitants, as the relatively large number of cases with a value of 0 for these variables could cause problems. The results (Appendix I and II) hardly deviate from the original model. The effect of access to other cities or borrowed size thus seem robust to the exact cut-off points used. Importantly, also the “own” density effect on the start-up rate remains consistent across the three countries.

Other possible concerns are institutional and geographical differences between Flanders and Wallonia distorting the results for Belgium. Indeed, these institutional differences may cause the significant negative effect of the squared distance to the nearest urban center: those municipalities relatively far from any urban center are generally located in Wallonia, where start-up levels are lower on average. Therefore, we reran the analyses for Belgium excluding Wallonia (Appendix III). We chose not to use a dummy indicating whether a municipality is Flemish or Walloon since we expect that the institutional differences do not only cause a difference in the level of the start-up rate but also in how certain explanatory variables impact the dependent variable. For example, as the urbanization level is much higher in Flanders, the mediating impact of the distance to urban municipalities may differ from that in Wallonia. In Flanders, most municipalities are influenced by some urban center, whereas this is not the case in Wallonia. For Flemish municipalities, only increasing distance from an urban center of at least 100,000 inhabitants have a significant negative effect on start-up activity. In addition, there seems to be a slight “distance-protection” effect from the largest urban centers, i.e., those of 250,000 inhabitants or more. Excluding Wallonia also turns the spatially lagged urbanization variable significantly negative, confirming our hypothesis that in Flanders, parallel to the Netherlands, competition effects between regions play a role. The larger size and lower population level of municipalities in the north of Sweden could distort the results for Sweden, both by increasing the volatility of the start-up rates and because these municipalities have very low population densities while most of the population concentrates in one relatively densely populated part of the municipality. In addition, the less dense road system in the north of Sweden may cause problems as we use Euclidean distances to calculate the distance to urban centers. To account for this, we excluded the north of Sweden and reran the analyses (Appendix IV). The results remain robust to this slightly different set-up of the model.

The goal of this study was to determine whether the relationship between urbanization and start-up activity differs between countries depending on the relative settlement patterns of these countries. Places do not operate in a vacuum, and to understand the effect of “own” density on start-up patterns, we need to account for the urban spillovers or borrowed size that they may experience from other places nearby. This may account for the empirical ambiguity in the relationship between urbanization and start-up intensity. Also, the impact of other places on start-up intensity is relevant in and of itself.

Without controlling for settlement patterns, urbanization has a significant negative effect on start-up activity in the Netherlands and Belgium, whereas the effect is insignificant for Sweden. After including a spatially lagged urbanization variable and variables measuring the distance to the urban centers, the effect of urbanization on start-up rates becomes significantly negative in all three countries. Also, it is of the same magnitude. This suggests that empirical effects of urbanization are indeed strongly impacted by the wider geographical context. More specifically for start-up research, it shows that start-up rates may be higher in urban areas but that this is associated with spatial sorting of people and economic activities and not so much with the urbanization economies these areas offer. In fact, after controlling for the supply of entrepreneurs, demand for products and the institutional environment, the benefits of start-up in a dense place (knowledge spillovers, increased potential for new combinations) seem to be outweighed by the additional costs (rents, labor costs).

The effects of spatial spillover or borrowed size are more diffuse across the countries, reflecting the different geographies and overall levels of density. In the Netherlands and Flanders, being surrounded by densely populated neighbors has a negative effect on local start-up activity; whereas in Sweden, the direct effect is positive. Increasing distance from an urban center has a consistent negative effect on start-up rates, and there is an additional penalty for distance from higher-tiered cities. This implies that a municipality does not have to be very highly urbanized itself to be conducive for start-up activity. Access to urban centers, however, is crucial. Yet, at a very large distance from an urban center, greater distance can also protect rural areas as it insulates firms from urban competition. Interestingly, the distance across which urban spillovers are felt differs between the three countries. This is in line with assumed differences in the perception of distance, possibly following from the settlement patterns in countries: People living in a more sparsely populated country such as Sweden are generally willing to commute further than people living in a highly urbanized country such as Belgium or the Netherlands.

This study, however, did not directly address the mechanisms through which the relative location of places influences start-up patterns. The results must thus be taken as stylized facts, and they can be supplemented by studies that consider the mechanisms more directly, for example, by assessing firm location and the geographical markets in which it is active. Also, it is plausible that different types of start-up—service vs. manufacturing, new vs. new branch, and opportunity vs. necessity—are impacted differently by national settlement patterns (Lavesson 2017). And while this explorative study focused on three illustrative countries, it would be interesting to study a wider variety of national settlement patterns.

A rural or urban area in the north of Sweden is not the same as a rural or urban area in the Netherlands or Belgium, or even in the south of Sweden. Logical as this may seem, this study is one of the first to explicitly study the impact of the geographical context on start-up patterns. Accounting for the relative location of places, we find that “own” density has a consistently negative effect on start-up intensity, while the access to other places has a generally positive effect although this is more diffuse. It comes to show that part of the entrepreneurship puzzle local policy makers struggle with lies outside of their control. The results imply that understanding the context in which your city is located may be as important as understanding the city itself. Urbanization economies extend far beyond the borders of local administrative units: the impact of major urban areas is felt over a long distance, and rural areas or smaller cities nearby major cities behave differently from those located in more isolated areas.