Objective Evaluate disparities in a Brazilian state by conducting an analysis to determine whether socioeconomic status was associated with the reported intimate partner sexual violence (IPSV) rates against women.
Design A retrospective, ecological study.
Settings Data retrieved from the Notifiable Diseases Information System database of the Ministry of Health of Brazil.
Participants All cases of IPSV (n=516) against women aged 15–49 years reported in the Notifiable Diseases Information System between 2009 and 2014.
Outcome measures The data were evaluated through an exploratory analysis of spatial data.
Results We identified a positive spatial self-correlation in the IPSV rate (0.7105, P≤0.001). Five high–high-type clusters were identified, predominantly in the Metropolitan, West, South Central, Southwest, Southeast and North Central mesoregions, with only one cluster identified in the North Pioneer mesoregion. Our findings also indicated that the associations between the IPSV rate and socioeconomic predictors (women with higher education, civil registry of legal separations, economically active women, demographic density and average female income) were significantly spatially non-stationary; thus, the regression coefficients verified that certain variables in the model were associated with the IPSV rate in some regions of the state. In addition, the geographically weighted regression (GWR) model improved the understanding of the associations between socioeconomic indicators and the IPSV notification rate, showing a better adjustment than the ordinary least square (OLS) model (OLS vs GWR model: R2: 0.95 vs 0.99; Akaike information criterion: 4117.90 vs 3550.61; Moran’s I: 0.0905 vs −0.0273, respectively).
Conclusions IPSV against women was heterogeneous in the state of Paraná. The GWR model showed a better fit and enabled the analysis of the distribution of each indicator in the state, which demonstrated the utility of this model for the study of IPSV dynamics and the indication of local determinants of IPSV notification rates.
- spatial analysis
- sexual violence
- violence against women
- intimate partner violence.
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Strengths and limitations of this study
The ecological design of the study allowed the identification of geographical areas and clusters in Paraná state with higher intimate partner sexual violence against women notification rates.
At the population level, the study design also enabled identification of the social and economic factors associated with higher intimate partner sexual violence against women notification rates.
As a limitation, the study findings are based on data from sexual violence notifications, which may reflect only a portion of the cases involving intimate partner sexual violence in Paraná state, since this crime is frequently undernotified.
We could not infer causality in this study and could only determine associations of the significant variables.
Intimate partner violence is the most common type of violence against women and is perpetrated by a partner or former partner. Sexual violence and intimate partner violence are major public health problems that occur worldwide and can damage the physical, sexual, reproductive, emotional, mental and social health of the victim and his/her family.1
According to global estimates by WHO, one in three women has suffered sexual violence,1 the majority of which occurs in the domestic environment, corresponding to 12 million people annually.2 In Brazil, sexual violence against women has been positively associated with a low family income, experience of sexual violence in childhood,3 and development of post-traumatic stress symptoms.4
Although frequent, estimating the magnitude and consequences of sexual violence is challenging because many women are silenced by shame, discrimination and fear of partner reprisals.5
A 2005 study conducted by WHO in 10 countries showed that the rate of intimate partner sexual violence (IPSV) among women aged 15–49 years ranged from 6.2 % in Japan to 58.6 % in Ethiopia. 1
Recent studies performed in public health services in Brazil have reported IPSV rates of 20.3% in women aged 15–49 years in the Southeast of the country6 and 5.7% in women aged 20–59 years in the state of Espirito Santo.4 Another study conducted in the city of São Paulo and 15 municipalities in the state of Pernambuco showed rates of 10.1% and 14.3%, respectively.7
Notification of violence against women remains a new process in Brazil and is conducted at health units. However, the woman is responsible for the decision to report the violence, to submit herself to medical examinations and even to perform an abortion if conception results from sexual violence.8
Data from the Ministry of Health of Brazil on IPSV notification rates involving women showed that the Southern region presented the second highest rate of this type of violence between 2009 and 2014. Among the states in the Southern region, Paraná ranked first in this category (17.6/100 000 women) with a figure higher than the national rate (10.4/100 000 women).9
Geospatial studies conducted in Brazil have identified areas that are vulnerable to domestic violence against women in municipalities in the states of Paraiba10 and Rondonia,11 where networks of social and economic relationships may favour or curb its occurrence.11 Studies investigating IPSV against women are scarce in the scientific literature, and to the best of our knowledge, no study has analysed the spatial distribution of IPSV against women and the associated geospatial indicators.
Determining the spatial distribution of IPSV against women and the socioeconomic indicators involved in this type of violence is the first step in identifying geographically vulnerable areas and priorities for the establishment of public policy investment and constructing instruments to prevent, identify and contain this type of violence.
This study evaluates regional disparities in Paraná state and performs analyses to determine whether socioeconomic status is associated with the sexual violence by intimate partner notification rates for women aged 15–49 years in the state of Paraná, Brazil, from 2009 to 2014.
Study design and location
This study was an ecological, retrospective study based on secondary data for the IPSV notification rates that used geospatial analysis techniques.
Paraná state is located in Southern Brazil (latitude coordinates 22°30′58′′ and 26°43′00′′ and longitude coordinates 48°05′37′′ and 54°37′08′′) and covers an area of 199 880 km2. This state is bordered by Paraguay and Argentina and the states of São Paulo, Mato Grosso do Sul and Santa Catarina. Paraná contains 10 geographical mesoregions subdivided into 399 municipalities (figure 1).
According to the 2010 Brazilian Census, Paraná state includes 10 444 526 inhabitants who live predominantly in urban areas (85.3%).12 The state of Paraná is ranked fifth in the Human Development Index (HDI=0.749) and is the fifth state ranked according to the economy in Brazil.13 Figure 1 shows the distribution of the HDI in the state of Paraná and its administrative regions.14 Notably, the economic development of the state is uneven. The Northern and Western areas of the state are more developed (with more cities with higher HDIs), as is the metropolitan area of the state capital (Curitiba). The centre and Southern areas are less developed than the rest of the state. This disparity is important for understanding the distribution of health outcomes, such as IPSV.
For this study, data for the number of notifications of IPSV (sex partners, including a spouse, ex-spouse, boyfriend, ex-boyfriend, girlfriend and ex-girlfriend) for both genders against women aged 15–49 years old per residence in the 399 municipalities of the state from 2009 to 2014 were obtained from the Notifiable Diseases Information System9 of the Ministry of Health. Since 2003, notification of violence against women has been compulsory in health services in Brazil.15
The population of each municipality according to age group was obtained from the Brazilian Institute of Geography and Statistics (IBGE).12 Five municipal socioeconomic and demographic indicators based on the last demographic census (2010) were formulated as follows: ‘population density (inhabit/km2)’ was obtained from the Paraná Institute of Economic and Social Development,9 whereas data on the ‘civil registry of legal separations (%)’, ‘women with higher education (%)’, ‘economically active women (%)’ and ‘average female income’ were obtained from the IBGE.12
We performed an exploratory analysis of spatial data to determine the spatial self-correlation measures of the IPSV rates. First, to minimise variation in the IPSV notification rates by city and the possible random fluctuations derived from the analysis of small populations, the empirical Bayesian estimator was used in the queen weights matrix in GeoDa, which considers all neighbourhoods that have a common frontier.16 17
This estimator calculates a weighted notification rate by considering regional variances and therefore allowing comparisons between different populations. In the state of Paraná, 364 (91.2%) municipalities have less than 20 000 inhabitants; thus, most cities are small, and the distribution of the phenomenon is heterogeneous. Furthermore, under-reporting of IPSV is an important problem, particularly in small cities.18
Using the Global Moran’s I statistic, spatial self-correlation was calculated based on the IPSV notification rate per 100 000 women for each municipality. Moran’s I varies between −1 and +1. Values greater or less than the expected Moran’s I value (E (I)=−1/(n−1)) indicate a positive or negative self-correlation, respectively. A positive spatial self-correlation indicates that neighbouring areas present values similar to those of the analysed area, and a negative spatial self-correlation indicates that neighbouring areas present values different from those of the analysed area. A Moran’s I value of 0 (zero) represents the hypothesis of spatial independence.19
The Global Moran’s I can hide local patterns of spatial association, since a negative Global Moran’s I values does not necessarily indicate the absence of a spatial correlation on a local level. To avoid this limitation, local indicators of spatial association were applied to identify significant cluster formation, which was visualised in choropleth maps. Spatial clusters were categorised according to the patterns and characteristics of the adjacent districts. High–high (HH) clusters are a set of districts with high rates that are surrounded by other districts with high reporting rates. Low–low (LL) clusters are groups of districts with low rates surrounded by low rate districts. The global and local spatial autocorrelation coefficients were considered significant when P<0.05.
Although Global and Local Moran’s I are well-known statistical techniques, they are univariate and do not consider multivariate effects. Thus, we chose to use regression models with and without control for spatial dependence.
Therefore, the ordinary least square regression (OLS) and geographically weighted regression (GWR) models were used to explore the relationships between the IPSV notification rates and independent variables.
Ordinary least squares
In the OLS regression analysis, we included all predictors within our secondary database that were previously shown to be associated with IPSV. To improve multicollinearity and the model’s performance, we iteratively conducted a sensitivity analysis and chose the model with the best Akaike information criterion (AIC)/Bayesian information criterion values and the lowest multicollinearity. The variables entered in the model were ‘women with higher education (%)’, civil registry of legal separations (%)’, ‘economically active–busy women (%)’, ‘population density (inhabitants/km2)’ and ‘average female income’.
In sequence, residuals from the global OLS model were analysed for spatial self-correlation using Moran’s I to evaluate the extent of the outcome that could be explained by the spatial component after modelling for predictors. The increase was not very large when we compared the OLS and spatial lag models. Thus, we chose to keep the classical regression.
Geographically weighted regression
Additionally, since the dependent variable presented strong (univariate) positive spatial self-correlation, we chose to use GWR to identify possible local associations and to demonstrate the spatial effect of the multivariate model. Thus, the coefficients of each predictor that were significant in the overall model were plotted to determine the impact of space on the outcome.
Compared with the OLS model, which presents constant regression coefficients in relation to the geographical space (stationarity), the coefficients in the GWR model are estimated locally from analysis of the spatial variability of the results in each area, which enables verification of the presence of spatial non-stationarity (ie, whether the relationships between regression variables vary in relation to the geographical space).20 Consequently, the GWR model generates a set of local linear regression models rather than a global model with estimates for each sample in space.21 The performance of the GWR model was evaluated based on the adjusted R2 indicators, AIC parameters and Moran’s I of the residues of both models.
The spatial self-correlation and the OLS model were processed using the GeoDa software V.126.96.36.199 (Spatial Analysis Laboratory, University of Illinois at Urbana-Champaign, Urbana, Illinois , USA),17 whereas the GWR model was implemented by GWR V.4.0.22 Choropleth maps were generated using the QGIS V.2.14 software.23
This study did not require ethical approval and consent from each individual since the data used were secondary and were available from government databases of online data. However, this study followed the national guidelines for research with human subjects.24
A total of 516 IPSV reports against women aged 15–49 years were recorded from 2009 to 2014. A mean annual rate of 2.93/100 000 women with IPSV against women occurred during the period, with municipal rates ranging from 0 to 23.3/100 000 women. According to the race/colour/ethnicity of the victims, the predominantly affected women were white (67.8%) and brown (20.0%). The predominant age groups were 30–39 years (34.3%) and 20–29 years (28.5%).
Regarding schooling, incomplete primary education (37.6%), complete secondary school (16.3%) and incomplete secondary school (12.2%) predominated. Only 6.4% of the subjects reported having a higher education. The main aggressor was the spouse (56.4%), followed by a former spouse (22.7%), former boyfriend (10.7%) and boyfriend/girlfriend (10.3%). The likely aggressor had suspected alcohol use in 52.1% of the cases. According to location, the violence occurred predominantly in the home (83.5%) or in a public pathway (8.1%). The majority of the cases were referred to as repetitive violence (69.4%). The assessed women were predominantly referred to an outpatient clinic (51.2%) or hospital for admission (7.9%). Occurrences evolved to evasion/escape or death in 1% and 0.6% of cases, respectively. The gender of the aggressor could not be identified due to the non-existence of this variable in the database.
Figure 2A shows the spatial distribution of the weighted rate of IPSV notifications classified according to the intensity grade. Of the 399 cities in the state of Paraná, rates greater than 1.79–6.55 were identified in 33.3% of the municipalities and were mainly distributed in the Metropolitan, West, South Central, Southwest, Southeast, North Central and North Pioneer mesoregions.
The IPSV notification rates presented positive spatial autocorrelation (Global Moran’s I=0.710519), showing that the IPSV notification rates in municipalities influenced this same rate in the neighbouring municipalities.
Figure 2B shows the spatial autocorrelation using the formation of the types of clusters presented in the state of Paraná according to the IPSV rate. Five HH clusters were identified, involving 19.5% of the state’s municipalities. Four clusters were located in the Southern region of the state, involving the Metropolitan, West, Southeast, South Center and Southwest mesoregions. Only one cluster was identified in the North mesoregion. The largest HH cluster encompassed municipalities located predominantly in the Metropolitan mesoregion.
As indicated in figure 1, further analysis of the data presented in figure 2B showed that although some municipalities involved in HH cluster formation presented high HDIs (0.73–0.82), the clusters predominantly presented municipalities with lower HDIs. Conversely, municipalities with high HDIs predominately displayed a LL pattern cluster, particularly in the North mesoregion.
Classical and OLS regression models (GWR) were used to identify the socioeconomic indicators most associated with the sites with the highest IPSV reporting rates.
According to these models, the indicators ‘civil registry of legal separations’, ‘economically active women’, ‘demographic density’ and ‘average female income’ were significant. The indicator ‘women with higher education’ was significant only in the GWR model. The correlation with the IPSV notification rate was negative in both models for ‘women with higher education’ and ‘civil registration of legal separations’ and positive for ‘economically active women’. However, the indicators ‘demographic density’ and ‘average female income’ presented different results (negative or positive correlations) according to the model used.
Compared with the OLS model results, the GWR model improved understanding of the associations between socioeconomic indicators and the IPSV reporting rate. The adjusted R2 coefficient increased from 0.95 to 0.99, the AIC decreased from 4117.90 to 3550.61 and Moran’s I of the residues increased from 0.0905 to −0.0273, showing a better fit of the GWR model (table 1).
Figure 3 shows the contribution of different indicators to the variation in the IPSV notification rate. The results were as follows: (1) the population density rate increased mainly in the Western mesoregion (figure 3A); (2) the rate of ‘economically active women’ increased in the Southeast Metropolitan, Eastern Centre and North Pioneer mesoregions (figure 3B); (3) the rate of ‘women with higher education’ decreased in the Western, Northwest, North central, Southwest, South central and Southeast mesoregions (figure 3C); (4) the rate of ‘average female income’ increased in the Western, Northern Pioneer, Central North and Eastern Central regions (figure 3D) and (5) the rate of ‘civil registry of legal separations’ decreased with the IPSV notification rate (figure 3E). The residuals of the model presented a random distribution throughout the state (figure 3F).
This study is the first to analyse the spatial distribution of the IPSV reporting rates and associated municipal indicators. The use of spatial analysis successfully identified clusters of IPSV rates against women and demonstrated that the phenomenon was heterogeneous in the state, with HH clusters distributed mainly in the Metropolitan, West, Center South, Southwest, Southeast and North central mesoregions. We identified important socioeconomic indicators associated with the IPSV reporting rates against women, which could contribute to understanding the phenomenon; these rates will serve as a subsidy for the identification of vulnerable populations and the elaboration and implementation of policies for the prevention and control of this type of grievance.
Demographic density has been shown to increase the likelihood of IPSV reporting rates. The positive association between demographic density and homicide has been previously demonstrated in this country25 26; however, other studies did not report this association.27–29 In our study, mesoregions with high HDI values, such as the Metropolitan, North Central and West, were involved in the HH clusters.
Our findings showed that the proportion of women with a higher education who were judicially separated contributed to the decrease in IPSV. Previous studies have shown that women with higher schooling and incomes are more likely to leave violent marriages.30
The average female income and the proportion of economically active women influenced the increase in the reports of IPSV, which contrasted with the results of previous studies. Low financial autonomy has been presented as a risk factor for sexual violence by intimate partners.31 32 Conversely, financial independence is a protective factor for physical and emotional violence.31 Recently, a decrease in the wage gap between men and women in the USA has led to a reduction in violence against women.33 In 2000, the United Nations (UN) integrated the millennial development objectives for the promotion of equality between the genders and the autonomy of women.34 The UN has published a report showing progress in this area.
In the 20th century, after the entry of women into the labour market, the family system in Brazil experienced a transition process in which male control based on the role as provider was held in check consistent with the occurrence of violence, including sexual violence.35
Acceptance of beatings by the wife has been presented as a risk factor for sexual violence.31 Daughters with parents involved in marital violence are more likely to suffer intimate partner violence,31 36 37 as are the offspring of offending abuse,32 suggesting that violence can spread for generations. This context may prevent women from verbalising complaints of violence to health professionals.38
Our regression analysis is based on city indicators and IPSV report rates available on national databases. Reliance on these data could limit the impact of this study. However, we have used the Bayesian estimator to minimise any inconsistencies. The reporting of violence against women is a new process in Brazil, and under-reporting remains a problem, either because of a lack of training and/or misunderstanding of its importance by health professionals18 or because the omission of victims.38 This fact can account for only some of the cases involving the problem of IPSV in the state of Paraná, resulting in a limitation of this study. However, identifying the panorama of IPSV in the regions and the municipal indicators involved in this type of injury is the first step in planning or even strengthening strategies of control and prevention.
Our study was developed in a Brazilian state with a high HDI, similar to those of developed countries, which allows generalising the results for similar areas, but mainly for those areas with economic and social disparities.
The reporting of violence against women is a new process in Brazil, and under-reporting remains a problem either due to lack of training and/or misunderstanding of its importance by health professionals18 or even omission by victims.38 However, identifying the panorama of IPSV in the regions and the municipal indicators involved in this type of injury are the first steps in planning or even strengthening control and prevention strategies.
In 2003, the Brazilian government formulated a National Plan of Policies for Women,39 which among other actions had the purpose of implementing a National Policy to Combat Violence against women and guaranteeing specialised services and a humanised care network.40
In 2015, the state of Paraná launched a protocol that unified care for people who suffered from some type of sexual violence outside the home environment.41 However, most health programmes and services do not have protocols for domestic violence cases and sexual violence against women by an intimate partner at present.35
Since most municipalities in the state do not have all the reference services of the network to combat violence against women (eg, specialised police stations and shelter houses), expansion of human resources and structures has become essential. Moreover, since violence against women is a paradigm that can propagate for generations, clarification for and guidance of women, children and adolescents should be a priority.
IPSV against women was heterogeneous in every state and was distributed throughout the Metropolitan, West, Central, Southwest, Southeast and Central North mesoregions. The maps generated by the GWR model were used to analyse the distribution of each indicator in the state, demonstrating the utility of this model in the study of IPSV dynamics and the identification of local determinants of the IPSV notification rates. The identification of areas vulnerable to IPSV and their respective determinants will serve to improve prevention strategies and strengthen public policies aimed to prevent and control IPSV.
Contributors KBF, ACJA, LA and MDdBC were involved in conceptualisation; KBF and LA were involved in the formal analysis; KBF, ACJA, OKN, SMP and MDdBC were involved in the investigation; KBF, LA and MDdBC were involved in the methodology; KBF and MDdBC were involved in project administration; KBF, ACJA, OKN, SMP, LA and MDdBC were involved in resources; LA was involved in the statistical analysis; MDdBC was involved in supervision and KBF, ACJA, OKN, SMP, LA and MDdBC were involved in writing (original draft, review and editing).
Funding This research received no specific grant from any funding agency in the public, commercial or not-for-profit sectors.
Competing interests None declared.
Patient consent Not required.
Provenance and peer review Not commissioned; externally peer reviewed.
Data sharing statement No additional data are available.
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