The underlying reasons behind the unprecedented increase of the mortality rates due to the opioid epidemics in the United States are still not fully uncovered. Most efforts have been focused on targeting opioids, but there is little information about vulnerable populations at high risk of opioid abuse and death. In this study, we used data from the Ohio Department of Health for deaths caused by prescription opioids from 2010–2017 to analyze the spatiotemporal dynamics of the opioid overdose epidemic. Our results showed a rapid increase in prescription opioid death rates among the white male population aged 30–39 but also a considerable increase among the black male population with an exponential growth trend. Our geospatial analysis suggests that the increasing rates of the opioid overdose epidemic in Ohio were driven by the epidemic hotspot areas. Our findings highlight the relevance of prioritizing public health measures targeting specific locations and vulnerable populations to mitigate the current opioids crisis.
The United States (US) is currently experiencing an opioid overdose crisis with an unprecedented magnitude. Adjusted for age, the opioid-related death rate of 21.7 deaths per 100,000 people in 2017, and 20.7 in 2018 were the highest worldwide1. According to the Centers for Disease Control and Prevention (CDC), 67,367 deaths by drug overdose occurred in the US during 2018, and 351,564 deaths were related to opioids resulting in 0.36 years of life expectancy lost in 20161,2. The major cause of death among people under 50 years old in the US in 2017 was drug overdose, exceeding the rates of death caused by motor vehicle and firearms3. Opioids have become a widespread cause of accidental fatal overdose, which historically were attributed to heroin and prescription opioid pain relievers. Recent reports show that overdoses caused by synthetic opioids (e.g., fentanyl and analogues) are emerging as a national public health emergency, as declared by the US Department of Health and Human Services in 20184.
National data on opioid overdose mortality rates show that the epidemic is not homogenously distributed within the US. Twenty states and the District of Columbia have reported age-adjusted drug mortality rates that are statistically higher than the national rate. Among these, West Virginia (51.5 deaths per 100,000 inhabitants), Delaware (43.8), Maryland (37.2), Pennsylvania (36.1.3), Ohio (35.9), and New Hampshire (35.8) had the highest age-adjusted drug overdose rates in 20181. Moreover, Ohio is one of eight states with a doubling of the opioid mortality rate every three years from 1999 to 2016, and recently has experienced an unprecedented number of deaths caused by unintentional drug overdose, especially deaths caused by synthetic opioids2,5. Specifically, there was a 169% increase from 1,544 deaths in 2010 to 4,157 deaths in 2017, and approximately 13,000 overdose events reversed by the use of naloxone.
Several reasons are attributed to the geographical disparity of the opioid overdose mortality6,7,8. Among the potential factors of the uneven distribution, special attention has been devoted to the association between the opioid overdose mortality and drug prescription rates, and the availability of medications to reverse overdose events (naloxone)8. This approach can be linked to the intervention measures implemented in these high opioid overdose burden areas to tackle the epidemic, which are focused on controlling prescription while increasing the availability of resources to treat the adverse effects of the overdose events9. Additionally, other studies also propose socioeconomic characteristics associated with the high-risk opioid overdose areas10. Health accessibility (primary care and mental health accessibility), unemployment rate, urbanicity, and availability of prescription vs. non-prescription opioids seem to be associated with high rates of opioid overdose mortality7,8. However, the reasons behind the uneven spatial distribution of the opioid epidemic in the US are still not well understood. Although the link between the number of opioid prescriptions and opioid overdose deaths has been observed, explanations about the rapid rise in the epidemic in specific areas remain incomplete, especially in areas where the number of opioid prescriptions is low and the determinants (i.e., drivers) of the epidemic have not been completely established11. Moreover, the epidemiological characteristics of the opioid public health crisis remain understudied and there is a lack of substantial spatial analysis for allowing health authorities to make decisions for resource allocation at small scales.
While most efforts have been focused on targeting opioids, there is little information about vulnerable populations at high risk of opioid abuse and death, where and what demographical groups are at higher risk, and what are the drivers boosting the epidemic of opioid overdose deaths in the recent years12.
In this context, geospatial statistical and epidemiological models are important tools for identifying the spatial and temporal dynamics of the epidemic13. Understanding the critical spatiotemporal characteristics of the opioid overdose crisis will provide valuable information to identify the potential socio-economic drivers of the epidemic as well as geographic areas where vulnerable populations are located, and where interventions should be implemented.
In this study, we used data from the Ohio Department of Health for deaths caused by prescription opioids from 2010–2017 to analyze the spatiotemporal dynamics of the opioid overdose epidemic in Ohio. The objective of the present paper is threefold, namely, to identify (i) the demographic groups in Ohio at higher risk of prescription opioid overdose death, (ii) the geographic areas in Ohio where the burden of overdose mortality is concentrated, and (iii) the temporal trend of the opioid epidemic in Ohio. The results from this study will inform public health authorities and clinical practitioners about which locations and groups should be prioritized for surveillance to improve public health response addressed to mitigate the current opioids crisis, not only in Ohio but also inform other parts of the country experiencing emerging epidemics, and even other countries of the world where opioid epidemics seems to be emerging.
General profile of the opioid overdose epidemic
Deaths by unintentional prescription opioids overdose in Ohio for 2010–2017 resulted in 11,790 cases (white population: 10,712 – black population: 1,078). Deaths have increased continuously from 653 in 2010 to 3,674 in 2017, with an exponential growth trend. Prescription opioid overdose mortality rates increased from 9.98 to 57.31 per 100,000 inhabitants from 2010 to 2017 (Table 1). The highest prescription opioid overdose mortality rates were found in the white male population aged 30–34, with 131.45 cases per 100,000 inhabitants, followed by males aged 35–39 with 120.48 cases per 100,000 inhabitants, compared to the 57.31 cases per 100,000 inhabitants for the total population in 2017 (Table 1). Figure 1 illustrates the temporal growth trends for race and gender categories and shows that black males were experiencing the fastest estimated annual increase (46.73%) of the opioid overdose mortality rate, compared to the total population rate (31.65%) during the period of study. For this specific race group, the highest rate was found in black males aged 35–39, with 109.55 cases per 100,000 inhabitants in 2017.
Spatial clustering analysis of the opioid overdose epidemic
We identified 12 geographical clusters (hotspots) of prescription opioid overdose mortality cases where most of the burden of the epidemic in Ohio was concentrated during 2010–2017 (Table 2). These 12 hotspots encompassed 21% of the population at risk (1,363,811) and contained 4,769 (40%) total deaths by prescription opioids overdose from 2010 to 2017. In 2017, mortality rates by prescription opioid overdose were almost three times higher within the hotspots compared with the outside areas, with 116.00 cases per 100,000 inhabitants within the hotspot areas and 40.49 cases per 100,000 inhabitants outside of the hotspots. The geographical locations of the identified hotspots are presented in Fig. 2. Most hotspots (Clusters 1, 2, 4, 6, 7, 9, 11, and 12) were located around the three major southwestern cities of Ohio (Dayton, Cincinnati, and Columbus). Three additional hotspots (Clusters 3, 5, and 8) were identified in the cities of Cleveland, Akron, and Youngstown, and one small hotspot (Cluster 10) was identified in the city of Toledo on the northern border with Michigan.
Space and space-time relative risk estimation
The spatial distribution of the relative risk (RR) of death by prescription opioid overdose is presented in Fig. 2A. RR ranged from 0 to 8.16, and was classified as lowest risk areas (RR < 0.50), low risk (RR: 0.50–0.80), intermediate risk (RR: 0.80–1.20), high risk (RR: 1.20–2.00), and highest risk (RR > 2.00). In 2017, the RR within the hotspot areas was significantly higher (average RR = 2.42, 95% confidence interval [CI] 2.15–2.68) compared to the non-hotspot areas (RR = 0.80, 95% CI: 0.77–0.84). Additionally, the RR was significantly higher than 1 in most of the hotspots except for Cluster 6 (RR = 2.45, 95% CI: 0.63–4.26), Cluster 11 (RR = 2.20, 95% CI: 0.77–5.28), and Cluster 12 (RR = 1.28, 95% CI: 0.76–1.81). The highest RR values were in Cluster 1 (RR = 3.61, 95% CI: 2.33–4.89) around the city of Dayton, followed by Cluster 3 (RR = 2.94, 95% CI: 1.83–4.05) in Cleveland, and Cluster 4 located in the Cincinnati area (RR 2.61, 95% CI: 1.90–3.31).
Temporal analysis of the RR of death caused by prescription opioid overdose identified a significant increase over time within the hotspot areas (RR change from 2010 to 2017: +10.17%, 95% CI: +4.82–+15.51%) (Fig. 2B). Conversely, RR in the non-hotspots areas was significantly decreasing (RR Change: −3.20%, 95% CI: −4.10–−2.31%). The highest RR increase was observed in Cluster 1, with an RR increase of 48.94% (95% CI: 25.72–72.16%). The only hotspot for which RR had a significant reduction was Cluster 6 located within the area of Columbus, Ohio (RR Change: −16.99%, 95% CI: −33.85–−0.12%).
Temporal trend analysis
Temporal trend analysis identified three significant changing trends of the opioids overdose epidemic in Ohio. Figure 3 shows the cumulative percentage difference between the observed growth rate of death rates by prescription opioid overdose and the expected counterfactual in the significant trimesters (dashed, black lines). The first trend was identified in January 2011 with a decreasing effect in the trajectory of the epidemic (p < 0.005). Conversely, two trends with an increasing effect in the mortality rate were identified in July 2013 and October 2015 (p < 0.005). The increasing trend identified in July 2013 had the highest impact in the temporal dynamics of the epidemic, with an estimated difference between the observed and expected changes in the mortality rate of +21.00% (95% CI: +6.10–+37.00%). This result indicates that in absence of any disturbance, we would have an expected decrease of the mortality rate of −3.00% (95% CI: −19.00–+12.00%) for each month, but in contrast we observed a monthly average increase of +18.00% starting in this time point (July 2013). Similarly, effects for the second trending increase in 2015 corresponded to a difference between observed and expected mortality rate change of +13.00% (95% CI: −3.00–+30.00%). Detailed results of temporal trending causal effect estimation can be found in Supplementary Table 1, and spatio-temporal dynamics of the opioid overdose cases are illustrated in Supplementary Video 1 in Supplementary Materials.
We combined a novel spatial epidemiology approach with data for prescription opioid overdose deaths from 2010–2017 from Ohio and determined that the opioid overdose epidemic is concentrated in specific locations and severely affecting specific demographic groups. We found that the burden of deaths related to prescription opioid abuse was concentrated mostly in the white male population aged 30–39, followed by black males aged 35–44, especially in Southwestern Ohio, with a remarkable exponential increasing trend. Sociodemographic risk factors have been related to substance abuse disorders by several studies conducted previously14. These studies found that age, gender, race, and economic factors have a significant impact in the risk of substance abuse disorders15. Moreover, the opioid use disorder (OUD) epidemic currently experienced in Ohio can be the result of a long complex series of epidemics related to substance abuse that have been reported in the U.S. since the early 20th century. These epidemics have several interconnected elements at individual and interpersonal level, as well as with the relationship between individuals, families and their communities14.
Opioid overdose deaths are often the result of a previous history of substance abuse, which often starts between the ages of 18 to 25 years16. Adolescents with a family history of substance abuse are 10-fold more likely to suffer drug abuse disorders in the future than other individuals14. Individuals aged 25–44 years may start using opioids for medical or recreational purposes, and then shift to more cost-effective substances like fentanyl17. Such early onset of substance addiction is consistent with our results, which show that the young adult population (25–39 years) was experiencing the highest burden of opioid overdose deaths, possibly in the last stage of an OUD history. Also, consumption of synthetic opioids such as fentanyl and analogs, which are the current leading substances associated with overdose deaths, is more frequent in white non-Hispanic males.
Our results suggest notable disparity among gender and racial groups. This could be due to the opioid overdose epidemic following a temporal trend that is comprised of three waves14,16. Briefly, the first wave of the opioid overdose epidemic, from 1970 to 1999, was driven by heroin overdoses, which showed a larger burden centered in the black population. The second wave, from 1999 to 2010, was mainly caused by prescription opioids often used for pain management therapy, which produced a steeper increase in death rates among the white population. This increase was driven in part by broader access to healthcare, marketing campaigns, and socio-economic determinants, as well as the marketing of opioid products to medical doctors, which was found to be associated with increased opioid prescribing and, subsequently, with elevated mortality from overdoses18,19. Finally, the third wave, which includes the current study time period (2010 to 2017), is mainly attributed to the combination of prescription opioids and the introduction of synthetic opioids16,18. Nationwide, this last wave has shown a similar increase in both racial groups (white and black)18.
Our results showed a rapid increase in prescription opioid death rates among the white male population but also a larger increase among the black male population. However, the underlying causes of these epidemiological trends differ among these demographic groups14,18. Misuse of synthetic opioids differs by gender and race. Moreover, previous analysis of healthcare accessibility among major racial groups suggests that black males are less likely to get appropriate treatment and effective medication for OUD. Black males were also reported to have a higher rate of overdose deaths caused by cocaine compared to other demographic groups14,18. However, this trend is rapidly changing, due in part by the current state of the opioid epidemic in which the price of synthetic opioids is decreasing while demand is increasing16. The access to addiction treatment and medications to reverse the effects of opioids addiction (naloxone) could also contribute to the racial disparity in the temporal trends of the opioid epidemic20.
We found a rapid and large increase in the rate of prescription opioids overdose death in the male population. Although, gender disparities for the OUD epidemics have shown that females are more likely to get prescription opioids than men14, the high amount of overdose deaths caused by synthetic drug overdoses since 2013 tends to obscure death rates caused by other types of opioids. The countermeasures to limit the effects of the opioid epidemic focusing on limiting prescriptions have resulted in declining overdose deaths by prescription opioids mainly in the female population16. Finally, females were found to be more likely to obtain a naloxone prescription than males21.
Our geospatial analysis suggests that the increasing rates of the opioid overdose epidemic in Ohio were driven by the epidemic hotspot areas. The results highlight the need for identifying areas with high and low risks when analyzing the overall epidemiological trends of the opioid crisis22. In fact, intrinsic spatial dynamics of epidemics identified in previous studies suggest that an overall decreasing trend in the epidemic at large geographical scales could mask local disparities with sustained or increasing burden of the epidemic in hotspot areas22,23. For example, whereas the RR slightly declined in the areas outside of the clusters identified, the highest RR was found in Cluster 1 (RR = 3.61), which was also the cluster with the highest temporal increase between 2010 and 2017 (RR increase: 48.94%). This area includes the city of Dayton, the city with the highest death rate due to drug overdose in the U.S. for 201724,25. Moreover, reasons for the spatial concentration of opioid overdoses in the southwestern counties could be partially explained by the high amount of opioids seizures recorded in Ohio, Kentucky and Indiana, which suggest that state borders may be areas where opioid consumption for non-medical purposes (especially illegally manufactured fentanyl) is common26. Geographic differences in the opioid demand are also linked to the historic substance abuse burden, exacerbated by areas where job and educational opportunities have been traditionally more difficult to access10.
The opioid overdose epidemic may continue to increase over time. Therefore, identifying social determinants is critical to mitigate the current growing phase of the epidemic27. Our temporal analysis identified two periods with significant increasing trends in death rates by prescription opioid overdose. Among these periods, the steepest increase in death rates was found in July 2013. An additional discrimination analysis by drug involved in the overdose showed that death rates due to opioids excluding fentanyl had a decreasing trend until mid-201328. From this time point, fentanyl-related overdoses started increasing mortality rates until 2017. Moreover, we identified an increasing trend in mortality rate over time, growing from 10.34 cases per 100,000 inhabitants in 2013 to 16.90 in 2014. The second significant increase trend in opioid related mortality rate was found during July 2015, potentially associated with the introduction of carfentanyl, which is an ultra-potent fentanyl analog known to be approved only for veterinary use29,30. The highest increase in mortality rates took place during this period, from 26.10 cases per 100,000 inhabitants in 2015 to 42.33 in 2016. These temporal dynamics of the opioid overdose epidemic are consistent with the time frame when the federal government classified opioid painkillers from Schedule 3 to Schedule 2 in 2014, limiting its access to both prescribers and patients. The abuse of opioids painkillers plateaued after this period, but this change also might have boosted heroin and fentanyl overdoses that increased significantly due to a rebound effect31. These results suggest that the opioid crisis is a complex epidemic, potentially caused by excessive prescription of pain reliever medications, but also driven by the recent inclusion of synthetic opioids for recreational use, especially involving fentanyl and analogs.
This research study has some limitations. Data from the Ohio Department of Health do not distinguish between prescription opioids for medical use and abuse by illicit manufactured synthetic opioids. Several reports suggest that many drug abusers are not aware that cocaine and heroin are being contaminated with fentanyl16, and deaths by overdose after consuming multiple drugs at the same time may be classified as opioid overdose. Additionally, we limited our causal trend analysis to data from January 2011 to December 2016. Some reports have indicated a decrease in deaths by opioid overdose in Ohio during the last semester of 2017 and early 2018, thought to be caused by decreased availability of carfentanyl in the illegal market and the wider availability of naloxone in Ohio and nationwide21,24. However, data for opioid overdose mortality data for 2018 are still not available, and there are no official reports for deaths in Ohio by drug overdose for 2018 currently available.
Despite these limitations, our study explored the epidemiological and spatiotemporal dynamics of the opioid overdose epidemic in Ohio from 2010 to 2017. We identified specific geographic areas in Ohio where the epidemic was concentrated during this time period. The methodology used and the findings derived from them are of fundamental importance, particularly for identifying and preventing the emergence of similar drug abuse epidemics in the country and worldwide10. For example, oxycodone, known to be one of the first prescription opioid used for pain management, is suspected to be the main driver of emerging substance addiction epidemics not only in Canada, UK, and Australia, but also in China, Brazil, Colombia, Egypt, Mexico, Philippines, Singapore, South Korea, South Africa, and Spain10.
Methods to eradicate the opioid epidemic include targeting the socio-economic and demographic drivers of the epidemic, together with projects to increase access to naloxone and the creation of safe places for controlled drug use to help avoid death and prevent the spread of other diseases10,27. Additionally, tighter controls on prescriptions and the flow of illicitly manufactured fentanyl to the black market are starting to force a declining trend in overdose death rates9,16. Strategies to monitor the amount of fentanyl diluted in other drugs and disseminating information among drug users may reduce consumption10. However, there is an undeniable need for more comprehensive strategies to fully understand the epidemic, including a strategy that focuses on potential differences among demographic groups, standardization of the guidelines for the formulation of prescription opioids, and appropriate training of medical personnel10, especially since an opioid epidemic could be a key driver of infectious disease outbreaks such as HIV, hepatitis C virus, and endocarditis32.
Data sources and demographic analysis
Data were provided by the Ohio Department of Health and included 20,938 unintentional deaths by drug overdose from January 1st2010, to December 31st, 2017 in Ohio. This dataset was filtered to include only deaths caused by prescription opioid overdose (International Classification of Diseases, 10th Revision (ICD-10) cause of death codes: T40.2, T40.4, T40.6) among the majority racial groups (white and black population) aged 20–64 years (more than 95% of cases were aged 20–64) to focus analysis on adults of working age. As a result, 11,790 deaths by unintentional prescription opioid overdose were included in the analysis. The dataset also included information about gender, race, and age of the deceased individuals. Cases were geolocated by zip code of residency using the American Community Survey conducted by the United States Census Bureau33.
Estimated population sizes were retrieved from the United States Census Bureau American FactFinder portal33 by race, gender, and age group for each year from 2010 to 2017 and aggregated by zip code. Specifically, population size for each year by zip code was determined using projections made from 2010 Census Bureau data to estimate the number of males and females for white and black populations across five-year age groups from age 20 to 64 years. Since population density is reported yearly, population by month and trimester were estimated using a non-parametric regression spline interpolation. Aggregated deaths by race, gender, and five-year period were merged with data on population density to compute opioid overdose death rates per 100,000 inhabitants in each demographic category. Population sizes, number of deaths, and death rates were also computed for each zip code and year for use in the spatial and spatiotemporal analyses.
Identification of high-risk groups was conducted using opioid overdose mortality rates by race and gender. Prescription opioid death rates were estimated using Poisson regression analysis to quantify the annual percentage change for each race-gender group, and to identify the group with the highest increase in death rate during the period of analysis. Demographic profiles of death rates and number of deaths by race, gender, and age group were used to determine which groups were most impacted by prescription opioid overdose.
Spatial clustering analysis of the opioid overdose epidemic
The spatial distribution of prescription opioid overdose deaths was analyzed using a spatial scan statistical analysis of data from 2010 to 2017, implemented in the SaTScan software34. We used scan statistics to identify geographical locations where the number of prescription opioid overdose deaths was higher than expected under the null hypothesis of a random spatial distribution of the deaths across the state. We refer to clusters of prescription opioid overdose deaths as hotspots. We analyzed death counts (from 2010 to 2017) using the SaTScan Poisson model with the size of the population at risk by location included as an offset. Briefly, identification of hotspots using the Poisson model implemented in SaTScan is achieved by testing each potential cluster against the null hypothesis that the distribution of cases was proportional to the population size (no clustering) using likelihood ratio and t-tests34. A hotspot was identified if the p-value was less than 0.05 and the grouping contained more than three zip code locations.
Space and space-time relative risk estimation
Spatial and spatiotemporal RR estimation of deaths caused by prescription opioid overdose at the zip code level were conducted using Bayesian models that were fit using an integrated nested Laplace approximation (INLA) implemented in the R-INLA software package35. INLA is a computational algorithm designed to approximate complex integrals involved in posterior distributions by using a latent Gaussian model approximation13. The number of deaths by prescription opioid overdose was modeled using a zero-inflated Poisson regression to accommodate excess zero counts in sparse area-specific data36 in the context of a Besag-York-Mollie (BYM) model37. The BYM model used incorporated spatially correlated random effects that were modeled using a conditionally autoregressive structure (i.e., neighboring zip codes have correlated random effects). A second unstructured random effect was included in the model, and its variance component was modeled with a diffuse gamma prior distribution. Spatial analysis was conducted by zip code on the total number of deaths from 2010 to 2017, while spatiotemporal analysis was conducted by zip code on monthly data from 2010 to 2017.
To identify areas with high risk of opioid overdose mortality rates, we computed the prevalence and average RR in 2017, and temporal changes in RR by zip code within hotspots and non-hotspots. The temporal change in RR was defined as the percent difference between the average RR for the last semester of 2017 and the first semester of 2010. Finally, smoothed surfaces of the estimated RR and temporal change in RR were mapped along with the identified hotspots. Maps were created using ArcGIS by Esri version 10.5 (http://www.esri.com)38, and basemaps were obtained from ESRI and National Geographic available at ArcGIS Online basemaps39.
Temporal trend analysis
Temporal trends of overdose death rates were identified using Bayesian interrupted time series analysis implemented in the CausalIimpact package in R40. In short, the analysis quantifies significant changing trends of the opioid overdose death rate (over a 12-month period) from the death rate expected in the absence of any disturbance of the opioid epidemic. Disturbances are assumed to be caused by external events that could positively (or negatively) influence death rates of prescription opioid overdoses over time (e.g., new government policies for reducing opioids prescriptions, new drugs available in the market).
Using this analysis, we modeled death rates for Ohio as a time series of monthly periods to estimate the monthly percent difference between the observed period and the (unobservable) change of death rates that would have occurred under the absence of any disturbance (called a counterfactual)40. The algorithm uses three sources of information to construct the counterfactual. The first source was a control time series given by the Ohio population at risk (aged 20–64) for each month, and the analysis assumes that in the absence of a positive or negative disturbance, overdoses are proportional to the population at risk. Second, the algorithm uses the death rates before a given time to estimate the alternative outcome without the effect of the disturbance. Finally, prior distributions of the outcome are used to include prior knowledge about the model using Bayesian regression. The three sources of information are combined using a state-space time series model. Death rates under the counterfactual model are computed from their posterior distributions, and the difference between the monthly percent change in the observed and counterfactual death rates are used to identify significant trends of the opioid epidemic.
Using this method, we simulated changes in the trajectory of the epidemic each month from January 2011 to December 2016 to identify the periods when the most significant changes occurred. Data from a period of 12 months before and 12 months after were used to estimate the observed and counterfactual percent differences in death rates of the epidemic. Then, estimated p-values for each month were grouped by trimesters to avoid short term variations, and non-contiguous periods, with p-values less than 0.005 selected to represent significant temporal trends in the epidemic41.
All data used in this study were in accordance with the ethical standards, following protocols for secondary data analysis, and with the approval of the Institutional Review Board (IRB) University of Cincinnati number CR01_2017–7637, and the Ohio Department of Health.
The datasets generated and analyzed during the current study are not publicly available due to privacy restrictions of sensitive data. However, unidentified datasets are available from the corresponding author on reasonable request and with permission of the Ohio Department of Public Health.
Code for all analyses are available within the article and its Supplementary Information.
Hedegaard, H., Miniño, A. M. & Warner, M. Drug overdose deaths in the United States, 1999–2018. (National Center for Health Statistics, 2020).
Kiang, M. V., Basu, S., Chen, J. & Alexander, M. J. Assessment of Changes in the Geographical Distribution of Opioid-Related Mortality Across the United States by Opioid Type, 1999–2016. JAMA network open 2, e190040–e190040, https://doi.org/10.1001/jamanetworkopen.2019.0040 (2019).
Kochanek, K. D., Murphy, S. L., Xu, J. & Arias, E. Deaths: Final Data for 2017. (National Center for Health Statistics, 2019).
The White House. Ending Americas Opioid Crisis, https://www.whitehouse.gov/opioids/ (2018).
Ohio Opioid Summary (March 2019). (National Institute on Drug Abuse (NIDA), 2019).
Schoenfeld, E. R. et al. Geographic, Temporal, and Sociodemographic Differences in Opioid Poisoning. American Journal of Preventive Medicine 57, 153–164, https://doi.org/10.1016/j.amepre.2019.03.020 (2019).
Dean, A. & Kimmel, S. Free trade and opioid overdose death in the United States. SSM - Population Health 8, 100409, https://doi.org/10.1016/j.ssmph.2019.100409 (2019).
Haffajee, R. L., Lin, L. A., Bohnert, A. S. B. & Goldstick, J. E. Characteristics of US Counties With High Opioid Overdose Mortality and Low Capacity to Deliver Medications for Opioid Use Disorder. JAMA Network Open 2, e196373–e196373, https://doi.org/10.1001/jamanetworkopen.2019.6373 (2019).
Penm, J. et al. Strategies and policies to address the opioid epidemic: a case study of Ohio. Journal of the American Pharmacists Association: JAPhA 57, S148–S153, https://doi.org/10.1016/j.japh.2017.01.001 (2017).
Humphreys, K. Avoiding globalisation of the prescription opioid epidemic. The Lancet 390, 437–439, https://doi.org/10.1016/S0140-6736(17)31918-9 (2017).
Stopka, T. J. et al. Opioid overdose deaths and potentially inappropriate opioid prescribing practices (PIP): A spatial epidemiological study. International Journal of Drug Policy 68, 37–45, https://doi.org/10.1016/j.drugpo.2019.03.024 (2019).
James, K. & Jordan, A. The Opioid Crisis in Black Communities. J Law Med Ethics 46, 404–421, https://doi.org/10.1177/1073110518782949 (2018).
Blangiardoa, M., Camelettib, M., Baiocd, G. & Rue, H. Spatial and spatio-temporal models with R-INLA. Spatial and Spatio-temporal. Epidemiology 4, 33–49, https://doi.org/10.1016/j.sste.2012.12.001 (2013).
Mohammad, J. S., Botticelli, M., Hwang, R., Koh, H. K. & McHugh, R. K. The Opioid Crisis: A Contextual Framework and Call for Systems Science Research. (working paper).
Jalal, H. et al. Changing dynamics of the drug overdose epidemic in the United States from 1979 through 2016. Science 361, eaau1184, https://doi.org/10.1126/science.aau1184 (2018).
Ciccarone, D. The triple wave epidemic: Supply and demand drivers of the US opioid overdose crisis. (2019).
Spencer, M. R., Warner, M., Bastian, B. A., Trinidad, J. P. & Hedegaard, H. Drug Overdose Deaths Involving Fentanyl 2011–2016. (National Center for Health Statistics, 2019).
Alexander, M. J., Kiang, M. V. & Barbieri, M. Trends in Black and White Opioid Mortality in the United States, 1979-2015. Epidemiology 29, 707–715, https://doi.org/10.1097/EDE.0000000000000858 (2018).
Hadland, S. E., Rivera-Aguirre, A., Marshall, B. D. L. & Cerdá, M. Association of Pharmaceutical Industry Marketing of Opioid Products With Mortality From Opioid-Related Overdoses. JAMA Network Open 2, e186007–e186007, https://doi.org/10.1001/jamanetworkopen.2018.6007 (2019).
Wu, L.-T., Zhu, H. & Swartz, M. S. Treatment utilization among persons with opioid use disorder in the United States. Drug and alcohol dependence 169, 117–127, https://doi.org/10.1016/j.drugalcdep.2016.10.015 (2016).
Guy, G. J. et al. Vital Signs: Pharmacy-Based Naloxone Dispensing — United States, 2012–2018., (2019).
Cuadros, D. F. & Abu-Raddad, L. J. Spatial variability in HIV prevalence declines in several countries in sub-Saharan Africa. Health & Place 28, 45–49, https://doi.org/10.1016/j.healthplace.2014.03.007 (2014).
Cuadros, D. F., Branscum, A. J. & Mukandavire, Z. Temporal stability of HIV prevalence in high-burden areas regardless of declines in national HIV prevalence in Malawi and Zimbabwe. Aids 32, 1381–1383 (2018).
Goodnough, A. This City’s Overdose Deaths Have Plunged. Can Others Learn From It? New York Times (2018).
Harm Reduction Ohio. Deadly mystery: Ohio’s carfentanil death rate 2000% higher than other states. (2018).
Center for Disease Control and Prevention. Increases in Fentanyl Drug Confiscations and Fentanyl-related Overdose Fatalities. (Center for Disease Control and Prevention, 2015).
Feinberg, J. in World View Vol. 573 (Nature, 2019).
Ohio Department of Health. 2017 Ohio Drug Overdose Data: General Findings (Ohio Department of Health, Columbus, Ohio, 2018).
O’Donnell, J., Gladden, M. R., Mattson, C. L. & Kariisa, M. Notes from the Field: Overdose Deaths with Carfentanil and Other Fentanyl Analogs Detected — 10 States, July 2016–June 2017 | MMWR. (Center for Disease Control and Prevention, 2019).
Fomin, D. et al. Human deaths from drug overdoses with carfentanyl involvement-new rising problem in forensic medicine: A STROBE-compliant retrospective study. Medicine (Baltimore) 97, e13449–e13449, https://doi.org/10.1097/MD.0000000000013449 (2018).
Lopez, G. The opioid painkiller and heroin epidemic, explained., https://www.vox.com/2015/10/1/9433099/opioid-painkiller-heroin-epidemic (2017).
Reardon, S. The US opioid epidemic is driving a spike in infectious diseases. Nature 571, 15–16, https://doi.org/10.1038/d41586-019-02019-3 (2019).
US Census Bureau.
Kulldorff, M. & Nagarwalla, N. Spatial Disease Clusters: Detection and Inference. Statistics in medicine 14, 799–810 (1995).
Rue, H., Martino, S. & Chopin, N. Approximate Bayesian Inference for Latent Gaussian Models by Using Integrated Nested Laplace Approximations. Journal of the Royal Statistical Society. Series B (Statistical Methodology) 71, 319–392 (2009).
Inferring lung cancer risk factor patterns through joint Bayesian spatio-temporal analysis. Cancer Epidemiology 39, 430–439, 10.1016/j.canep.2015.03.001 (2015).
Besag, J., York, J. & Mollié, A. Bayesian image restoration, with two applications in spatial statistics. Annals of the Institute of Statistical Mathematics 43, 1–20, https://doi.org/10.1007/BF00116466 (1991).
ESRI. ArcGIS 10.x. Redlands, CA, USA: ESRI. (2004).
ESRI. “Topographic” [basemap]. “World Topographic Map”, http://www.arcgis.com/home/item.html?id=30e5fe3149c34df1ba922e6f5bbf808f (2012).
Brodersen, K. H., Gallusser, F., Koehler, J., Remy, N. & Scott, S. L. Inferring causal impact using Bayesian structural time-series models. Annals of Applied Statistics 9, 247–274 (2015).
Benjamin, D. J. & Berger, J. O. Three Recommendations for Improving the Use of p-Values. The American Statistician 73, 186–191, https://doi.org/10.1080/00031305.2018.1543135 (2019).
Mapbox. Mapbox GL JS 1.3.x. Washington, D.C., San Francisco, CA. (2010)
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Hernandez, A., Branscum, A.J., Li, J. et al. Epidemiological and geospatial profile of the prescription opioid crisis in Ohio, United States. Sci Rep 10, 4341 (2020). https://doi.org/10.1038/s41598-020-61281-y