Abstract
Metropolitan cities can serve as laboratories of sustainable development by experimenting with innovative sustainability programs while leveraging the advantages of metropolitan areas. With the importance of cities’ sustainability efforts, scholars have increasingly explored what factors motivate local governments to implement voluntary sustainability programs by focusing on internal government and community characteristics. However, what is missing in the previous discussion is whether city governments respond to sustainability efforts by other government entities, especially neighboring local governments. Drawing on institutional and policy diffusion theories, we analyzed the sustainability programs of 251 suburban cities in 66 metropolitan areas. We find that suburban cities are likely to consider sustainability efforts of central cities in the same metropolitan area when determining the extent to which they implement their sustainability programs. However, they are not necessarily responsive to sustainability efforts of nearby suburban cities. Our research sheds light on how local governments’ sustainability policy decisions are affected by their relationships with other local governments. It also provides policy implications for the important role of central cities in facilitating collective sustainability efforts in metropolitan areas.
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Notes
Scholars usually define the central city as the largest city in a given metropolitan area and all other cities in the same metropolitan area as suburban cities (e.g., Homsy and Warner 2015; Madden 2003, Savitch, Collins, Sanders, and Markham 1993). Similarly, OMB characterizes central cities as more significant places than other cities in metropolitan areas in terms of population and employment and uses names of central cities (up to three) to title metropolitan divisions in order of descending population size (OMB 2000). Following the widely used distinction, here, we refer to the first named city in the name of a metropolitan statistical area (MSA) as a central city and all other cities in the MSA as a suburban city.
The survey was originally sent to both county and city governments with more than 2500 population. Since our paper focused on how suburban city governments respond to neighboring suburban governments as well as central city governments, we include responses from city governments only.
Our sample suburban cities are not from the following states: Maine, New Hampshire, Rhode Island, Vermont, Indiana, North Dakota, South Dakota, Wisconsin, Arkansas, Washington DC, Kentucky, Louisiana, Mississippi, West Virginia, Alaska, Hawaii, Idaho, Montana, New Mexico, and Wyoming. The number of suburban cities in those states accounts for total 11.48% in population.
More detailed comparative descriptive statistics between our sample and population suburban cities will be provided upon request.
For simplicity, we included estimation results using the inverse distance weigh matrix that considers all suburban cities as neighbors (e.g., no cutoff distance) only. The results using other spatial weight matrices are similar and can be provided upon request.
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Appendix: determining a spatial weight matrix
Appendix: determining a spatial weight matrix
There are, in large, two ways of specifying the spatial weight matrix: (1) binary weight, where wij = 1 if the geographical distance between \({\text{location}}_{i}\) and \({\text{location}}_{j}\) is within a certain cutoff distance, otherwise 0 and (2) the inverse geographical distance between \({\text{location}}_{i}\) and \({\text{location}}_{j}\) if they are within a certain cutoff distance, otherwise 0 (Anselin and Le Gallo 2006). In either way, the weights matrix is usually row-standardized, such that \(\sum\nolimits_{j} {w_{ij} = 1}\) (Drukker et al. 2013).
Given our focus on metropolitan areas, we relied on the land area size of MSAs included in our sample to determine the cutoff distance within which cities are considered as neighbors. For example, average land area size of MSAs in our sample is about 2318 km2 (about 48 km radius) with minimum 38 km2 (about 6 km radius) and maximum 15,612 km2 (about 124 km radius). It implies that the maximum distance between two suburban cities in the same MSA is about 96 km on average. Taking this into account, we estimated our empirical models by using seven different spatial weight matrices: binary matrices with cutoff distance 50 km, 100 km, and 150 km, respectively, and the inverse distance matrices with cutoff distance 50 km, 100 km, 150 km, and no cutoff distance limit, respectively. Table 4 provides a summary of statistics for the empirical models using the seven different spatial weight matrices for our two dependent variables, respectively. Moran’s MI statistics test the hypothesis of no spatially autocorrelated disturbances, while LM-lag statistics test the hypothesis of no spatial lags (Zafra-Gómez and Chica-Olmo 2019). As shown in Table 4, the binary weight and the inverse distance matrices produce similar results for the number of program measure. However, for the breadth of program measure, Moran’s MI statistics indicate greater likelihood of disturbances to be spatially autocorrelated when using spatial matrix using no cutoff distance (p > 0.10), supporting our use of the SAR model that controls for spatial errors (Zafra-Gómez and Chica-Olmo 2019). The Akaike information criterion (AIC)s provide similar results across different cutoff distances, while the smaller AICs of the models using the inverse distance matrices suggest better model fits. Taken all these together, we determined to use inverse distance matrices using 50 km cutoff and no cutoff distance and then compared the results to ensure consistency of our findings across these two different scenarios.
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Ji, H., Tate, M.P. Spillover effects of central cities on sustainability efforts in a metropolitan area. Policy Sci 54, 95–121 (2021). https://doi.org/10.1007/s11077-020-09411-1
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DOI: https://doi.org/10.1007/s11077-020-09411-1