Rural Environmental Concern: Effects of Position, Partisanship, and Place

Authors


  • The Communities and Forests in Oregon (CAFOR) project was supported by a grant from the Disaster Resilience for Rural Communities Program, which is part of the National Institute of Food and Agriculture program of the U.S. Department of Agriculture (Award #2010-67023-21705). Preliminary field data collection was funded by a graduate field research grant from the Mazamas Foundation and Stevens was partially supported by the National Science Foundation under Grant No. 0801544 in the Quantitative Spatial Ecology, Evolution and Environment Program at the University of Florida. The Ketchikan and Southeast Alaska surveys received support from the USDA Rural Development program. Puget Sound surveys were funded by the U.S. Environmental Protection Agency, the National Oceanographic and Atmospheric Administration (National Marine Fisheries Service), and the College of Liberal Arts at the University of New Hampshire. Other Community and Environment in Rural America project surveys have been supported by grants from the Ford Foundation, Neil and Louise Tillotson Fund, the Office of Rural Development in the U.S. Department of Agriculture, and the Carsey Institute at the University of New Hampshire. The UNH Survey Center conducted all telephone interviews for these surveys, while the Carsey Institute provided logistical and administrative support.

Abstract 

The social bases of environmental concern in rural America resemble those for the nation as a whole, but also reflect the influence of place. Some general place characteristics, such as rates of population growth or resource-industry employment, predict responses across a number of environmental issues. Other unique or distinctive aspects of local society and environment matter as well. We extend earlier work on both kinds of place effects, first by analyzing survey data from northeast Oregon. Results emphasize that “environmental concern” has several dimensions. Second, we contextualize the Oregon results using surveys from other regions. Analysis of an integrated dataset (up to 12,000 interviews in 38 U.S. counties) shows effects from respondent characteristics and political views, and from county rates of population growth and resource-based employment. There also are significant place-to-place variations that are not explained by variables in the models. To understand some of these we return to the local scale. In northeast Oregon, residents describe how perceptions of fire danger from unmanaged forest lands shape their response to the word conservation. Their local interpretation contrasts with more general and urban connotations of this term, underlining the importance of place for understanding rural environmental concern.

Introduction

Rural communities often depend more directly on their environment and natural resources than larger, diversified cities. When the environment or resources change, rural places face strong pressures and yet more constrained choices (Dunlap 2010; Molnar 2010). Some of their constraints are social, including historically grounded perceptions about society–environment relations. Understanding how place-specific conditions influence environmental perceptions can be critical for changing communities that need to adapt as historical society–environment relations no longer hold (Devine-Wright 2013).

Ching and Creed (1997) emphasize the importance of place—both its metaphoric and geographic aspects—in shaping rural identity. Substantial work has been done on the social-psychological concepts of place attachment and place identification (Devine-Wright 2013; Kyle et al. 2004; Nielsen-Pincus et al. 2010; Raymond, Brown, and Weber 2010; Robbins et al. 2009; Rollero and De Piccoli 2010; Scannell and Gifford 2010). These dimensions can influence people's perceptions or behavior toward their environment.

We also know that the sociological bases of public perceptions about environmental issues in rural areas broadly resemble those identified for the United States as a whole. On rural as well as national surveys, education and political orientation predict responses about environmental problems from local to global in scale (Hamilton and Keim 2009; Hamilton, Colocousis, and Duncan 2010). Gender and age effects are widely reported; race effects tend to be issue-specific (Dietz, Stern, and Guagnano 1998; Jones and Dunlap 1992). Commonalities between urban, suburban, and rural residents could increase with the blurring of value and belief differences (Lichter and Brown 2011), partly reflecting demographic change as ex-urbanites move to the country.

Changing demographics contribute to shifting views of the environment (Gosnell and Abrams 2011; Nielsen-Pincus et al. 2010; Robbins et al. 2009; Sharp and Clark 2008). Other place characteristics including local environment and resource-environment relations affect environmental views as well (Brehm, Eisenhauer, and Krannich 2006; Hamilton et al. 2010; Hamilton and Keim 2009; Krannich, Petrzelka, and Brehm 2006; Stedman 2006; Stedman and Hammer 2006). Individual case studies can highlight aspects of environment–society relations that influence local concerns (Freudenburg and Gramling 1994). Expanding these into generalizations requires comparative data across many case studies. Certain general place characteristics, such as rates of population growth or employment in natural-resource industries, have shown impacts on environmental or resource issues (Gosnell and Abrams 2011; Hamilton et al. 2010; Henly 2012). Other relatively distinctive aspects of local environment, history, policy and regulations, land ownership, culture, or economy also affect perceptions, behavior, and resource management.

Previous research modeled both general and unique place effects, together with effects from individual characteristics, using data from a series of surveys conducted in 2007 for the Community and Environment in Rural America (CERA) initiative (Hamilton et al. 2010). Survey responses to environmental questions vary with respondent characteristics, much as expected, and also exhibit an interaction effect of education by political party similar to that observed with climate-change questions (Hamilton 2008; Hamilton and Keim 2009). In addition, environmental views are influenced by county rates of unemployment, population change, and natural-resource-based employment. Adjusted for measured individual and place characteristics, analysis shows significant place-to-place variation caused by countless other ways in which places differ.

This work follows a long tradition of research on the social bases of environmental concern (Van Liere and Dunlap 1980), which now ranges from cross-national analyses (e.g., Marquart-Pyatt 2012; Pampel and Hunter 2012) down to the local level in rural America (e.g., Brehm et al. 2006; Stedman 2006; Stedman and Hammer 2006; Petrzelka, Krannich, and Brehm 2006). Social-bases research commonly starts from background or positional factors such as age, gender, ethnicity, education, and income, together with worldview, ideology, or values indicators that tend to be correlated with social position (e.g., Dietz, Dan, and Shwom 2007; Dietz, Fitzgerald, and Shwom 2005; Dunlap, Xiao, and McCright 2001; Guagnano and Markee 1995; Jones and Dunlap 1992; Klineberg, McKeever, and Rothenbach 1998; Olofsson and Öhman 2006; Xiao and McCright 2007).

Inglehart (1995) linked values with social position by suggesting that environmentalist values flourish under “postmaterialialist” conditions of affluence. Inglehart and Baker (2000) developed this idea into a less linear path, more nuanced by place. Traditional values such as those in rural communities often persist in the face of demographic change, creating a distinct form of “modern” societies. Cross-national comparisons offer some support for a postmaterialist connection of comfort with environmentalism, but less so when subgroups within nations are considered—the wealthiest subgroups are not necessarily the most environmentalist (Brechin and Kempton 1994; Dunlap and York 2008; also see Dietz et al. 2005; Givens and Jorgenson 2011). For the United States in particular, ideological or political factors now show more consistent effects than social position in predicting individual levels of environmental concern (Hamilton et al. 2010; McCright and Dunlap 2011b).

Education, knowledge, and risk perceptions gain prominence where technical issues enter mainstream discussion (e.g., Krosnick et al. 2006; Leiserowitz 2006; Slimak and Dietz 2006; Viscusi and Zeckhauser 2005; Whitfield et al. 2009, Wood and Vedlitz 2007). Variations in risk perceptions account for some social-position results. For example, women often show higher concern regarding technology-driven risks. The disparity reflects women's higher assessments of personal and family dangers, and men's (especially, white males’) higher confidence in their own knowledge (Davidson and Freudenburg 1996; Finucane et al. 2000; McCright and Dunlap 2011a; Xiao and McCright 2012). Age effects are also observed, with older respondents expressing lower levels of concern. Cohort differences provide one explanation (Van Liere and Dunlap 1980). Environmental topics gained 1970s counterculture significance, grew prominent through media attention and major federal legislation (Clean Air Act, Clean Water Act, Endangered Species Act), and became integrated with modern school curricula. The future impacts of environmental problems such as climate change could affect age differences in risk perceptions as well.

Some research has tested whether rural versus urban residence predicts environmental concern. The heterogeneity of rural places (Freudenburg 2007) and the blurring of rural values or identity including newcomer–old-timer components (Abrams and Bliss 2013; Gosnell and Abrams 2011; Lichter and Brown 2011) contribute to mixed answers on this question. Case studies comparing several regions can address heterogeneity by describing what makes regions different, as illustrated by work on offshore oil development in coastal California, Louisiana, and Florida (Freudenburg and Gramling 1994; Gramling and Freudenburg 1996, 2006; Hamilton, Safford, and Ulrich 2012). When many places are compared, an alternative approach is to use measured characteristics of place as possible predictors. Ideally such place effects are evaluated while controlling for individual-level effects as well (e.g., Hamilton et al. 2010; Safford, Ulrich, and Hamilton 2012).

In this article we take a layered methodological approach, looking first at one regional study and then 11 others for context, to replicate and extend earlier research on society–environment relationships in rural communities around the United States. The analysis begins in northeast Oregon, where our survey asked both general and locally focused environmental questions. Some of the general questions have also been asked in other regions, providing a unique multiregional perspective. Analyzing these data highlights both overarching patterns and place-to-place variations. To understand the place-to-place variations calls for a return to the local level, illustrated by the northeast Oregon case.

The CAFOR Project in Oregon

In 2010 an interdisciplinary research team began a study of Communities and Forests in Oregon (CAFOR). The study focuses on three counties (Baker, Union, and Wallowa, combined population below 50,000) in the remote and mountainous northeast corner of the state (Figure 1). Almost half the land is managed by the federal government, including the Wallowa-Whitman, Umatilla, and Malheur National Forests; Hells Canyon National Recreation Area; and the Eagle Cap Wilderness. Private industrial timber interests own a smaller but economically important fraction as well. Forest products from public and private lands, historically the economic mainstay of this region, have recently experienced hard times. Timber production fell drastically during the last two decades, led by a decline of more than 90 percent in federal land harvests. Overall harvest decline coupled with global competition, mill closures, and rising costs for ranchers caused economic shocks that rippled throughout these three counties. National trends toward the divestment of large timber holdings, separating manufacturing and land ownership while consolidating mill infrastructure, have been felt here as well. More broadly, this region exemplifies a transitional mix of livelihoods tied to declining resource-based industries, alongside growing but not dominant amenity-based development. Similar transitions to varying degrees occur elsewhere throughout rural America today (Abrams and Bliss 2013; Gosnell and Abrams 2011; Krannich, Luloff, and Field 2011; Nielsen-Pincus et al. 2010; Robbins et al. 2009; Wilson 2006; termed “amenity/decline” places in the typology of Hamilton et al. 2008).

Figure 1.

Map of the CAFOR Study Region in Northeast Oregon.

Attracted by the area's natural amenities and available land, some retirees and people who work remotely or have independent wealth made new homes in this region. At the same time, rising real estate prices and lack of family living-wage jobs have left many young residents unable to afford land, forcing some to move away or change livelihoods. Other long-term residents adapt by subdividing, selling, or leasing their land to newcomers. Although there has been some rise in tourism, jobs in service and accommodation tend to be seasonal, not necessarily replacing the wages or benefits of forest-industry jobs. Partly reflecting socioeconomic shifts, conditions on forest lands are changing too, raising worries about wildfire. Among the changing economic and social conditions are some divisive environmental issues. Wind power presents one visible and controversial new development. Also controversial has been the reintroduction of wolves, which affects ranchers, game, and livestock, particularly in Wallowa County (Hamilton, Hartter, et al. 2012).

CAFOR aims to characterize the interconnected socioenvironmental changes taking place in this region, including how local residents perceive change and take action to adapt. One component involved a telephone survey of residents in the three-county region. Questions repeated core items from the CERA studies, supplemented by others developed for this region. Trained interviewers at the University of New Hampshire Survey Center conducted 1,585 interviews lasting about 10 to 15 minutes each during September and October 2011. We selected land-line phone numbers at random within each of the three counties to obtain a cross-section of the public (the overall response rate was 48 percent, calculated by the RR4 standard defined in AAPOR 2006). The survey oversampled forest landowners, who might hold views different from those of the general public. Probability weights (Lee and Forthofer 2006) compensate for this oversampling, and allow minor adjustments based on comparison with census-estimated age, sex, and race tables for this region. Weighting also corrects for design bias related to household size and county population.

Table 1 lists environmental questions on the Oregon survey. Some of these (rules, conserve, and climate) address general topics and have been used on other surveys. Conventionally environmentalist responses to these questions prove less popular in northeast Oregon than nationally, but the same result occurs in many resource-dependent rural areas. Other questions in Table 1 (wind, wolves, and lands) have salience in northeast Oregon, where wind power, the reintroduction of wolves, and management of public lands are subjects of handmade billboards. The CAFOR survey also named seven potential problems, asking whether respondents thought each posed a serious threat to themselves or their community. Tabulations of responses from each county, including comparisons with forest landowners and national benchmarks, appear in Hamilton, Hartter, et al. (2012).

Table 1. CAFOR (Northeast Oregon) Environmental Beliefs and Concerns, with Weighted Response Percentages (N = 1,585)
  1. Simplified coding shown here corresponds to the models in Tables 2, 3, and 5; see Hamilton, Hartter, et al. (2012) for more complete response breakdowns by county, and comparison with national results.
  • Rules:Have conservation or environmental rules that restrict development generally been a good thing for your community, a bad thing, or have they had no effect here? Coded 1 if good thing (23%), 0 otherwise.
  • Conserve:For the future of your community, do you think it is more important to use natural resources to create jobs, or to conserve natural resources for the future? Coded 1 if conservation more important (21%), 0 otherwise.
  • Climate:Which of the following three statements do you personally believe? That climate change is happening now, caused mainly by human activities; it is happening now but caused mainly by natural forces; or climate change is not happening now. Coded 1 if happening now caused mainly by humans (37%), 0 otherwise.
  • Wind:Which do you think should be a higher priority for the future of this country, increased exploration and drilling for oil, or increased use of renewable energy sources such as wind and solar? Coded 1 if renewable energy higher priority (56%), 0 otherwise.
  • Wolves:Which of the following four statements about wolves in eastern Oregon comes closest to your personal beliefs? Wolves should be eliminated from eastern Oregon, limited hunting of wolves should be allowed, wolves should not be hunted but landowners compensated, or wolves should not be hunted and no landowner compensation is needed. Coded 1 if wolves should be eliminated (34%), 0 otherwise.
  • Lands:When managing public lands, do you think we should give higher priority to meeting the needs of the local community, or broader needs and interests of America? Coded 1 if local needs higher priority (75%), 0 otherwise.
  • For each of the following, do you think that these problems pose a serious threat to you or your community? Coded 1 if serious threat, 0 otherwise.
    • Forest:Loss of forestry jobs or income (85%)
    • Insects:Insects (76%)
    • Fire:Wildfire (75%)
    • Move:Community changing as too many people move in or leave (44%)
    • Divide:Dividing and selling portions of large forest properties (43%)
    • Warming:Global warming or climate change (39%)
    • Cutting:Overharvesting or heavy cutting of timber (34%)

Position, Partisanship, and Place in Oregon

Results from regression of the first six environmental items (defined in Table 1) on individual characteristics and indicators for county appear in Table 2.1 Respondent's political party (coded –1 for self-identified Democrats, 0 for independents, and +1 for Republicans) dominates other predictors in these models. Republicans are less likely to perceive local benefits from environmental rules, to favor natural resource conservation for future generations, to believe that climate change is being caused by human activities, or to give wind and solar energy a higher priority than oil drilling. They are more likely to favor elimination of wolves from eastern Oregon, and to think that local needs should have priority over national interests in managing public lands.2

Table 2. Individual Characteristics and County of Residence as Predictors of Views on General and Local Environmental Issues in Northeast Oregon
Dependent Variables
PredictorRulesConserveClimateWindWolvesLands
Individual      
  1. Coefficients and tests are from weighted logit regression models.
  2. * p < .05.
  3. ** p < .01.
  4. *** p < .001.
Female–.268.170.095–.009–.258.152
Age in years–.007–.025***–.013*–.011*.007–.010
Newcomer.222.239.489*.403*–.814***–.407*
Own forest.258.259–.078–.024.288.030
Education.327***.034.254**.181*–.417***–.151*
Party–.735***–.782***–1.003***–.975***.686***.356***
Education×party.008–.183–.376***–.059.074.188*
County      
Baker–.057.065.216.277–.152–.033
Wallowa.293–.745**–.081.266.555**.320
Union
Intercept–.879*–.193–.110.484–.908*1.388***
Estimation1,4141,4141,4141,4141,4141,414
sample      

Newcomer status (having lived in northeast Oregon for less than 10 years) is the third-most consistent predictor in Table 2. Newcomers, commonly from more urban or suburban places, express greater support for conservation and the idea of anthropogenic climate change. They less often favor elimination of wolves, and tend to prioritize national interests ahead of local needs in land management. Similar newcomer–old-timer divisions arise in other rural communities where natural amenities attract in-migration (Hamilton et al. 2010). In northeast Oregon newcomers are no different from old-timers in terms of education, but they are somewhat more likely to be Democrats, and much more likely to be young. The newcomer effect in Table 2 (and Table 3) represents the net effect of this status if we held education, politics, and age constant.

Table 3. Individual Characteristics and County of Residence as Predictors of Perceptions about Environment-Related Threats in Northeast Oregon
Dependent Variables
PredictorForestInsectsFireMoveDivideWarmingCutting
Individual       
  1. Coefficients and tests are from weighted logit regression models.
  2. * p < .05.
  3. ** p < .01.
  4. *** p < .001.
Female.205–.576**.207.535***.105.356*–.018
Age in years.011.007–.005–.019***–.008–.012*–.003
Newcomer–.242–.244–.274–.158.178.255.180
Own forest.483.327.180–.026–.239–.014–.260
Education–.053.052–.042–.110–.030.026–.210**
Party.120.066–.078.021–.309***–1.133***–.497***
Education×party.242*.054.105.051.107–.069–.140
County       
Baker–.452*–.274–.112–.312–.393*–.122–.653***
Wallowa.483*–.042.256.203.000–.243–.403*
Union
Intercept1.101*1.097**1.356***.572–.031–.010–.184
Estimation1,4141,4141,4141,4141,4141,4141,414
sample       

Education (coded –1 = high school or less, 0 = technical school or some college, 1 = college graduate, and 2 = postgraduate degree) is the second-most consistent predictor in Table 2. The odds of conventionally environmentalist responses increase with education (at least, among Democrats and independents) for most of these items. A negative education-by-party interaction effect occurs with respect to climate, as expected from earlier studies (Hamilton 2008, 2011, 2012; McCright and Dunlap 2011b). Among Democrats and independents, education has a positive effect on belief that climate change is happening now, caused mainly by human activities. Education has a weak or negative effect on this belief among Republicans. Although the climate question asks about physical reality, many people form beliefs about this reality based on what they perceive to be its policy implication—that if anthropogenic climate change is real, then government intervention is needed. The land question invokes ideological position as well, and shows an interaction with opposite sign but similar meaning: education increases the odds of prioritizing local needs over national interests among Republicans, but not among Democrats.

Controlling for these individual predictors, we also see place effects in the form of differences between counties. For example, wolf packs in this region live mainly in Wallowa County, where proportionately more residents favor their elimination. Wallowa County also has the greatest exposure to public forest lands—51 percent of land within the county is public and managed by the federal government. As discussed later, many people believe that misguided conservation plans exacerbate the hazard of wildfire.

Table 3 provides results from regressing responses about environment-related threats on the same set of predictors. Loss of forestry jobs, insects, and wildfire are seen as serious threats by 75 to 85 percent of our respondents. Table 1 gives these percentages, and Table 3 shows that such concern is not partisan, nor is it related to most other demographics. These results emphasize that “environmental concern” has multiple dimensions. The social bases for northeast Oregon residents’ strong concern about forestry jobs, insects, and wildfire do not resemble those for more conventionally environmentalist issues in Table 2. Residents articulated this distinction in conversations with the researchers, emphasizing the importance of forest health while distancing their own views from those attributed to urban “environmentalist” others.

Concern about climate change (warming) shows a wide partisan divide, confirming its wedge-issue status (Hamilton 2012; McCright and Dunlap 2011b). To a lesser degree, concerns about subdivision of forest properties (divide; this often involves higher-intensity timber cutting, then resale of the land in smaller parcels for development or for hobby farms and ranches) and overcutting (cutting; in this context, likely to be part of the same sales process when timber owners liquidate assets) have some partisan basis as well.

County differences show place effects after controlling for other factors. Wallowa County residents are more likely, and Baker County residents less likely, to see threats to their communities from loss of forestry jobs. These differences reflect their resource situations. Wallowa County has more commercial and productive forest land, but mill infrastructure has steeply declined.3 Baker County on the other hand has less public forest land available or marketable for commercial harvest. People in both Wallowa and Baker Counties were unlikely (compared with Union County) to see a threat from overcutting, but their similar responses on that item arise for different reasons: for Wallowa residents the problem is not overcutting but too little cutting, associated with economic loss and fire danger. Overcutting is not problematic in Baker County either, but that is partly because forests account for a smaller fraction of the landscape and livelihoods.

Thus, the individual background factors that predict responses on local and global environmental issues in northeast Oregon broadly resemble those identified nationally and in other rural regions. More idiosyncratic place effects remain visible, however, in the contrasts between neighboring counties.

Replication across 12 Regions

Two earlier articles (Hamilton and Keim 2009; Hamilton et al. 2010) analyzed place effects in data from more than 9,000 CERA interviews representing seven U.S. rural regions (19 counties), surveyed in 2007. From 2008 to early 2012, under continuations of CERA and related projects, researchers conducted more than 13,000 additional interviews in 12 mostly different regions (38 counties, parishes, boroughs, or census areas—hereafter termed “counties” for brevity).4 Table 4 summarizes the 2008–12 surveys, including CAFOR in northeast Oregon. The particular regions studied were not selected at random, but according to substantive interest and goals of individual projects. Overall, the regional selection aimed for socioeconomic and geographic diversity. We targeted coastal regions in some surveys to complement the predominantly inland locations of earlier CERA work.5 Although the selection of regions is not random, researchers used random sampling and probability weighting to obtain representative samples within each region, and checked them against regional census profiles.

Table 4. Community and Forest in Oregon (CAFOR), Puget Sound, and Community and Environment in Rural America (CERA) Surveys Conducted by Carsey Institute Researchers, 2008–12
  • Northeast Oregon (CAFOR)
  • September–October 2011: Baker, Union, and Wallowa Counties in northeast Oregon (n = 1,585)
  • Puget Sound
  • January–February 2012: King, Kitsap, Mason, and Pierce Counties, in the Puget Sound area of Washington (n = 1,302)
  • Appalachia (CERA)
  • November 2010–January 2011: Harlan and Letcher Counties in coal country of Kentucky (n = 1,020)
  • Columbia River (CERA)
  • January–February 2011: Clatsop County, Oregon, and Pacific County, Washington (n = 1,023)
  • Downeast Maine (CERA)
  • August–September 2009: Hancock and Washington Counties, on the northeast coast of Maine (n = 1,518)
  • Gulf Coast Florida (CERA)
  • August–September 2010: Bay, Franklin, and Gulf Counties along the eastern Gulf Coast of Florida (n = 1,005)
  • Gulf Coast Louisiana (CERA)
  • Late July–September 2010: Plaquemines and Terrebonne Parishes in coastal Louisiana (n = 1,017)
  • Ketchikan, Alaska (CERA)
  • June–August 2010: Ketchikan Gateway Borough and Prince of Wales census area in Southeast Alaska (n = 509)
  • North Country (CERA)
  • June 2010: Coos County, New Hampshire, Essex County, Vermont, and Oxford County, Maine, adjacent in northern New England (n = 1,852)
  • Olympic Peninsula (CERA)
  • October–November 2010: Clallam and Grays Harbor Counties, on Washington's Olympic Peninsula (n = 1,013)
  • Southeast Alaska (CERA)
  • November–December 2010, with a small number of interviews in February 2011: Haines, Juneau, Sitka, Skagway, Wrangell, and Yakutat Boroughs, along with the Hoonah-Angoon and Petersburg census areas, all in southeast Alaska (n =1,033)
  • Upper Michigan (CERA)
  • August 2008: Alger, Chippewa, Luce, Mackinac, and Schoolcraft Counties, on Michigan's Upper Peninsula (n = 1,008)

Researchers have presented results from individual surveys in more than 30 reports (Carsey Institute 2013) and articles (Hamilton et al. 2012; Henly 2012; Safford and Hamilton 2011; Safford et al. 2012; Ulrich-Schad, Henly, and Safford 2013), which describe the individual study sites. Detailed tabulations of survey responses can be found in those sources. This section presents the first integrated analysis combining all of the 2008–2012 surveys, placing the northeast Oregon results of Table 2 in broad context.

Table 5 shows mixed-effects logit regression of the questions labeled rules, conserve, and climate (as defined in Table 1) on individual and place characteristics.6 Gender, age, education, and political party all show significant effects, in the positive or negative directions expected from previous research. Other things being equal, women are more likely to support conservation for the future instead of using resources now, and to believe that climate change is happening now, caused mainly by human activities. Older respondents are less likely to hold either view. Support for environmental rules, resource conservation, and belief in anthropogenic climate change all are more likely among better educated respondents, and less likely among Republicans. These education and partisan effects echo many previous studies, but here extend to locally relevant environmental questions in rural areas, controlling for local conditions. Rules assesses perceptions of benefits from environmental rules in respondents’ own communities. Conserve is a generational question as much as an environmental one. Climate invokes ideological beliefs about government, although these are not in the question itself or the scientific-physical reality. Typically, the climate question gets the most partisan response.

Table 5. Individual and Place-Level Predictors of Views on Environmental Issues across 38 Counties in 12 Regional Surveys.
Dependent Variables
PredictorRulesConserveClimate
Individual   
  1. Coefficients and tests are from mixed-effects logit regression models with random intercepts for each county. Number of counties, surveys, and estimation sample size vary depending on where a particular question was asked.
  2. * p < .05.
  3. ** p < .01.
  4. *** p < .001.
Female–.045.246***.136**
Age in years.002–.006***–.018***
Education.293***.067**.182***
Party–.389***–.387***–.860***
Education×party–.142***–.123***–.275***
County   
Population change.014*.015–.001
Unemployment rate–.006–.002.007
Resource employment (fixed)–.301**–.240–.203
Fixed intercept–.831***–.469.683**
Random intercept   
Standard deviation.255***.355***.249***
Counties/38/1234/1131/10
surveys   
Estimation12,33211,23210,031
sample   

Basic logistic regression models, such as those in Tables 2 and 3, focus on the logit or log odds (L) favoring one category of dependent variable y:

display math(1)

The log odds that y equals 1 for the ith observation are modeled as a linear function of the independent variables (x1i, x2i, etc.):

display math(2)

The intercept (β0) and slope coefficients (β1x1i, β2x2i, etc.) in [2] are fixed, or constant across all observations in the data. In contrast, mixed-effects logit models such as those in Table 5 model the log odds that y equals 1 for the ith observation (individual) and the jth cluster (county), as fixed effects from the independent variables (x1ij, x2ij, etc.) plus a random intercept (u0j) that could be different for each county:

display math(3)

Coefficients in Table 5 are maximum-likelihood estimates of the β parameters in Equation (3).7 The random intercepts (u0) take on many different values (one for each county) in these models. Table 5 gives their estimated standard deviations, which all show significant variation. Random slope coefficients are possible in mixed-effects models as well, but in testing many alternative specifications we found no evidence supporting their inclusion. Random slopes complicate these models without significantly improving their fit.

The negative education-by-party interactions in Table 5 mean that for all three dependent variables, environmental concern rises with education among Democrats, but does not rise and may even decline with education among Republicans. Education-by-party (or similar) interactions have been widely observed regarding climate-change-dependent variables (Hamilton 2008, 2011, 2012; Hamilton and Keim 2009; Kahan, Jenkins-Smith, and Braman 2011; Kahan et al. 2012; McCright 2011; McCright and Dunlap 2011b). They have less often been reported regarding nonclimate environmental concerns (Hamilton et al. 2010). Biased assimilation (Corner, Whitmarsh, and Xenias 2011; Lord, Ross, and Lepper 1979; Munro and Ditto 1997) and other differently described but conceptually similar processes, through which people selectively acquire information that supports their preexisting beliefs, may help to explain this phenomenon of information-elite polarization (Hamilton 2012). The ubiquity of political main and interaction effects in Table 5, as in Table 2, reflects national polarization across a range of environment- or science-related questions (e.g., Dunlap et al. 2001; Gauchat 2012; McCright and Dunlap 2011b).

Table 5 also shows that in counties with more rapidly growing population (measured as the rate of change from 2000 to 2010), people are more likely to perceive benefits from environmental rules that restrict development. Conversely, where population is shrinking, people see less benefit from such rules. This intuitively reasonable place effect is visualized in Figure 2, which collapses more than 13,000 responses into 38 counties, graphing the weighted percentage of respondents who favor environmental rules against the rate of county population change. A robust regression line depicts the county-level trend, consistent with the positive logit coefficient in Table 5.8 Figure 2 replicates Figure 6 (based on independent data) in Hamilton et al. (2010).

Figure 2.

Weighted Percentage Agreeing That Environmental Rules Have Been a Good Thing for Their Community, Graphed against Rate of Population Change in 38 Counties of 12 Regions. Shown with Robust Regression Line.

A negative coefficient in Table 5 indicates that approval of environmental rules tends to decline with the proportion employed in resource-based industries. Figure 3 visualizes this relationship in simplified form, again collapsing weighted survey responses by county. Figure 3 replicates Figure 4 in Hamilton et al. (2010).

Figure 3.

Weighted Percentage Agreeing That Environmental Rules Have Been a Good Thing for Their Community, Graphed against Log Percentage Employed in Resource-Based Industries in 38 Counties of 12 Regions. Shown with Robust Regression Line.

The 38-county dataset is strongly clustered, motivating our mixed-effects modeling approach. Random intercepts in Equation (3) allow for heterogeneity or differences in the mean response from each county. Even when values of all measured predictors are equal, odds of a particular response are higher in one county than another, because of the countless unmeasured differences between those places. Standard deviations of random intercepts in Table 5 show leftover but statistically significant county-to-county variation on all three environmental-concern measures. The next section revisits northeast Oregon to understand what that means.

Understanding Random Intercepts

Figure 4 graphs estimates of the random intercepts on conserve, averaged for all respondents in each of 11 survey regions (conserve was not asked in a 12th region, Puget Sound). Most of the variation comes from two regions, northeast Oregon and the Ketchikan Gateway Borough–Prince of Wales census area of Alaska. Negative random intercepts indicate that, even after adjustment for individual and place characteristics, support for resource conservation is notably lower in those two regions than elsewhere.

Figure 4.

Mean of Random Intercepts by Region, from the Conserve Mixed-Effects Model in Table 5. (No Data from Puget Sound on This Item.)

The CAFOR research team returned to northeast Oregon in summer 2012 to present survey results for discussion at public and stakeholder meetings. One topic that often drew comments was the question conserve, which asks whether people think it is more important for their community to use natural resources now to create jobs or to conserve resources for future generations. A number of residents remarked that they interpreted “conservation” to mean locking up land with access limitations and little or no tree harvesting, letting forests grow wild or unmanaged. This is a particularly contentious view involving the current state of forests, their management, and the heritage of working lands (Abrams and Bliss 2013). Although certain resources elsewhere, such as fish populations off Downeast Maine (largest positive intercept in Figure 4), would grow healthier without harvesting, northeast Oregon forests are different. A dramatic reduction in cutting, particularly in areas where fire has been excluded, leads to changes in forest structure, fire regimes, species assemblages, and riparian conditions. A century of fire suppression in the country's national forests (suppressing over 99 percent of unwanted wildland fires during initial attack; see Dale 2006) has contributed to unnaturally dense stands with high fuel loads, supporting an increasing number of large, intense wildfires (Agee 2003; Hessburg, Agee, and Franklin 2005; Langston 1995; Raffa et al. 2008; Westerling et al. 2006). Vulnerability rises as a result of insect outbreaks, overmature trees, or high stand density (Fairbrother and Turnley 2005; Shindler and Toman 2003). Decades of insect and disease mortality contribute to present-day fuel loads and stand conditions that support large, severe fires (Hessburg et al. 2005).

Upward trends in wildfires in recent years have made them a concern in western communities historically dependent on forests and their ecosystems, or among the growing population that lives on a wildland-urban interface (Barbour et al. 2005; Dale et al. 2001; Huston 2005). Our northeast Oregon discussants emphasized they do not support heedless overharvesting, but believe that the term conservation, which some associate with urban and left-leaning environmentalists unaware of local forest and community conditions, might imply curtailed or severely limited cutting. This contrasts with their own vision of stewardship and forest-community interconnection. According to this vision, true “conservation” should reduce the threat of wildfire while also producing economic benefits. Feelings on this point were particularly strong in Wallowa County (see Table 2), which contains the highest proportion of federal forest land, and where there have been several recent large wildfires originating on federal land.

The largest negative random intercept for the rules model belongs to Ketchikan, Alaska (not shown). Environmental rules in that area are associated with government restrictions on access and harvesting in Tongass National Forest (Safford et al. 2011) and the 1997 closure of a pulp mill that had been dumping sludge and wastewater. The intercept for northeast Oregon on the rules item also is negative, but less so than for Ketchikan.

Regarding climate, the third dependent variable in Table 5, a large positive intercept (not shown) occurs with our survey of North Country residents in northern Vermont, New Hampshire, and Maine. In that snowy region a long-term trend toward warmer, shorter winters provides tangible evidence of climate change (Hamilton and Keim 2009).

Conclusions

In rural places that sit at the uneasy crossroads between traditional resource-based production and new economies and cultures of aesthetic landscape consumption and diversified economies, ideas of landscape become increasingly important and contested (Lichter and Brown 2011; Walker and Fortmann 2003). Environmental value priorities shift along with changing livelihoods and the newcomer–old-timer mix (Huddart-Kennedy et al. 2009; Jones et al. 2003). Case studies of particular rural regions can describe their character in some depth, qualitatively associating details of place with perceptions about environment and resources. Representative national surveys can step back to generalize about broader patterns, but they lack statistical power to resolve local details. Our hybrid approach, embedding regional case studies into multiregional analysis, aims to keep both special details and common patterns in view.

This analysis began with northeast Oregon, where local issues involving wind power, wolves, and public land management exhibit individual predictors similar to those for beliefs about global climate change. Other issues involving threats to local forests and forestry, however, evoke strong concern without education or partisan divisions. We also see differences between neighboring counties that reflect details of their environments and resources.

Placing the Oregon survey in a multiregional context yields a step-back perspective on place effects. Local rates of population change and resource employment predict individual perceptions of environmental rules in these data, much as they had in an earlier multiregional study. People in areas with growing population and low rates of resource-based employment are more likely to approve of environmental rules that restrict development, findings consistent with Inglehart and Baker's (2000) account of postmaterialism conditioned by place.

Integrated modeling highlights both patterns and notable exceptions. Returning to northeast Oregon, we found an explanation for one notable exception in how people of that historically forest-dependent region interpret the word conservation. They associate this term with no-harvest policies believed to heighten risks from insects and wildfires, while curtailing forestry-based livelihoods that have been the region's staple. More generally, they associate “conservation” with urban environmentalists who do not understand local conditions. The term urbanormativity (Thomas et al. 2011) is not common in local discourse, but could be applied to the hegemonic urban values perceived and contested by many rural residents.

Ching and Creed (1997) observe that social science focusing only on demographics tends to overlook the importance of place in shaping rural experience. Our analysis takes this to heart by examining both factors, starting with the better known demographic influences. Net of demographics, broad place characteristics also have demonstrable effects. Statistically removing demographic and broad place effects illuminates variation that needs interpretation through more specific details of each place—such as the dangers perceived from fire suppression and no-harvest policies in northeast Oregon. Different details affect other regions, where understanding also requires awareness of local conditions. Examples from CERA include the contrasting imperatives of oil and tourism-based livelihoods in Gulf Coast Louisiana and Florida (Hamilton et al. 2012), or of neighboring amenity-growth and declining-resource counties in Downeast Maine (Safford and Hamilton 2011). Historically rooted connections between environment and society shape outlooks in many rural communities, affecting the prospects for policies and new adaptation paths.

Footnotes

  1. 1

    Weighted logit regression directly applies sampling weights to estimation of parameters, standard errors, and tests. Results more realistically represent target populations within each region. For example, Wallowa County has a smaller population than Union or Baker, but we intentionally sampled it at a higher rate. Weighted analysis adjusts percentages, regression coefficients, and other calculations so that Wallowa responses have no more than proportionate impact.

  2. 2

    Political party enters all regression models in this article both through its main effect and through its interaction with education. Main effects of party are interpreted as effects for a person with technical school or some college education (education = 0). Similarly, main effects of education are interpreted as effects for a person self-identified as politically independent (party = 0).

  3. 3

    Over the past 20 years, all four of the industrial-scale mills in Wallowa County closed down, compared with three of five in Union, and three of five in Baker (Hamilton, Hartter, et al. 2012).

  4. 4

    Most of these counties, parishes, etc., are classified as nonmetropolitan, in keeping with CERA's rural focus. A few, such as Washington's King County or Louisiana's Terrebonne Parish, are metropolitan, but there too the natural environment and resources hold central importance for the local economy and culture.

  5. 5

    A companion paper (Hamilton and Safford 2013) examines a set of specifically ocean-related environmental questions asked on the coastal-region surveys listed in Table 4.

  6. 6

    Three measured county characteristics derive from U.S. census data: population change from 2000 to 2010, as a percentage; unemployment rate, averaged for 2001–10; resource employment, log10 of employment in agriculture, forestry, fishing, hunting, or mining as a percentage of those employed in all industries. Values are for 2010 or, where those are unavailable, estimated by regression of nonmissing 2010 values on 2001–2007 values.

  7. 7

    Both individual characteristics such as age and county characteristics such as population growth appear among the x variables with fixed effects in Table 5. Although these models look different from the two-level formulation commonly used by multilevel modeling programs, the mixed-effects and multilevel-modeling approaches are mathematically similar. In practice, both are estimated through reduced-form equations along the lines of Equation (3) (Rabe-Hesketh and Skrondal 2012).

  8. 8

    The obvious outliers in Figures 2 and 3 are two southeast Alaska boroughs, Yakutat and Wrangell, where small survey subsamples allow more erratic variation in survey percentages. Robust regression lines resist influence by outliers, and do not assume normality (Hamilton 2013). If we conduct individual-level analyses with the full integrated dataset, it makes no practical difference if we set aside the smallest counties, so we kept these in for Table 5.

Ancillary