disease mapping contains a set of statistical methods , which leads to generate accurate maps based on estimations of incidence , prevalence , and mortality of diseases . the oldest example of disease mapping is the address of cholera victims based on distance from water resources , which was presented in 1854 by john snow . due to importance of geographic distribution of disease rates in determination of risk factors , the most important aims of disease mapping contains describing spatial variation in prevalence of diseases in order to formulate hypothesis about causes of diseases , specification of high risk areas which needed increased notice and interference , generating an accurate map of disease risk in area for the purpose of better resource allocation , and risk estimation as well as producing disease atlase . there are different models and methods to develop maps of diseases including simple statistic illustration , informal methods , basic models , bayesian models , multilevel models , etc . bayesian approach to disease mapping consists of prior information about variation in disease rates , in addition to observed events in each area . it also could consider spatial pattern of disease in which closer geographic areas have more similar disease rates . bayesian models in disease mapping comprise variously wide range with every one of them has its own formulation , characteristics , advantages , and disadvantages . several studies were conducted about comparison of these models . however , except a few and limited studies , disease mapping models were not compared , and their general condition was not investigated . clayton and kaldor made comparisons about a limited set of models ( empirical bayesian and full bayesian models ) . they concluded that in spite of some differences among relative risk estimations in all methods , the order of relative risk is similar in the whole mapping area . other efforts have been carried out to find the sensitivity analysis of full bayesian models that are confined to a limited range of bayesian models . regarding the importance of empirical and full bayesian models , this paper describes and compares three bayesian models in study of relative risk estimation of suicide in counties of ilam province during 18 months from march of 2007 till october of 2008 . it can begin from safe and preventable behavior and end up to sever and unpreventable ones . according to the world health organization report , the worldwide number of suicide attempts leading to death was one million people annually , and the number of suicide commitment was 20 - 30 times more than this . it is also estimated that around 1,530,000 million people will die due to suicide , and 10 - 20 times more than this figure will commit suicide by the year2020 . it means that , averagely , one death due to suicide per 20 seconds and one suicide commitment per one to two second will happen by the year 2020 . lithuania and russia have the first ranks of suicide in the world . in these countries 46 and 41 suicidesper 100,000 ( one hundred thousand ) people have been committed suicide in these countries respectively . suicide as a social anomaly has a high prevalence in iran too . according to reports from welfare organization of iran , international statistics indicates that suicide rate in iran was 9 per 100,000 people , which contributed 1% of total number of deaths . recently , among all provinces of iran , ilam province has shown one of the highest suicide rates . this province located in the west of iran contains eight counties , and its population has been 545,787 people in year 2006 . there are some differences among its counties according to weather , cultural , and social conditions . in addition , some of the counties near the border of iraq have more post - war problems of 8-year iraq - iran war for a long time . therefore , because of importance of suicide as a complex psychological phenomenon , influenced by individual and environmental factors , investigation and comparison of suicide rate in all counties of ilam province seems necessary and worthwhile to study . concerning the importance of suicide and its high rate in ilam province and existence of only some descriptive reports about suicide incidence , it is essential to investigate geographical variation of suicide incidence rates among counties of ilam province using advanced statistical models . in this applied ecological study , suicide data of ilam province collected by ilam university of medical science during 18 months from march of 2007 till october of 2008 were analyzed . relative risk of a disease is calculated by use of proportion of having a disease in a group with exposure to a risk factor to a group without this risk factor . in this study , we consider relative risk as proportion of the cases committed suicide to expected numbers . data analysis was carried out using gamma- poisson , log - normal , and bym bayesian models in winbugs software . estimates from each model were compared with one another as well as with standardized mortality ratio as a classic non - bayesian model . the results of bayesian models were compared by use of deviance information criterion ( dic ) . first of all , regarding the importance of these methods , specific properties , and some differences among them , it is essential to explain briefly theoretical principles , advantages , disadvantages , and characterization of each model . the first step to evaluate a disease incidence within an area is to estimate the expected rate of incidence in that area . the proportion of observed cases to expected one is called standardized mortality ratio ( smr ) . in studies related to diseases incidence , we use the proportion of observed to expected disease incidence , which is called standardized incidence ratio ( sir ) . this ratio is an estimation of relative risk within each area . in order to utilize this method , the map should be divided into n non - overlapped adjacent areas ( i = 1 , 2 ,  , oi and ei are the number of observed and expected events in i area , respectively . during the study , ei was assumed constant and known and calculated by multiplying the overall crude incidence rate by the area population or its estimation . , it is assumed that the number of events between areas are independent and follow poisson distribution with mean eii . therefore , the likelihood for oi is calculated by : also , logarithm of likelihood function is : so , the estimation of maximum likelihood is : although use of smr and sir is so common , there is some substantial shortcoming related to these estimations . to overcome these difficulties , hierarchical bayesian models play an important role in modeling the complexity of data structure in spatial epidemiology and can overcome smrs shortcomings . in addition to observed numbers , bayesian approach in disease mapping contains prior information about geographical variation of disease rates in whole map . it can be also considered disease spatial correlation ( the tendency of nearer areas to the same rates of disease ) . this model assumes that the number of deaths in areas follow a poisson distribution with mean eii . the prior distribution for relative risks is also considered gamma ( a , b ) . to obtain posterior distribution , gamma prior distribution for relative risks is combined with poisson likelihood . so , relative risk have posterior distribution gamma(a + oi , b + ei ) with mean   which . thus , posterior mean for area i is weighted average of smr for area i and overall relative risk that weights are conversely related to smr variance . if the observed and expected counts are high , the estimator tends to smr , but when they are low , it tends to prior mean . 2 . even if the real distribution of relative risks is gamma , this model can estimate mean and variance using maximum likelihood method , which is more valuable than moment method . although gamma prior distribution for relative risk is proper from mathematical point of view , it could be limiting because of difficulty with entering covariates . log - normal model is more flexible than gamma- poisson model for relative risks of disease : in this model , vi is included in order to consider spatial correlation and similarity of adjacent areas . this model was introduced by clayton and kaldor and extended by besag , york , and mollie , and its formulation is described as : log(i ) =  + ui + vi in this model , relative risk parameter is splitted into three components : 
  : trend component that is overall level of relative risk.ui : ( ( spatial overdispersion ) spatial correlated heterogeneity ) : it is logical that the close areas have similar relative risks . to take this similarities into account , the random variable ui which is uncorrelated with other { uj } sis included in the model . for this component , spatial correlation structure is used where estimates for relative risk in each area are dependent on adjacent areas . the conditional autoregressive model proposed by besag et al . is : that ,   and if i and j were adjacent , wij = 1 , otherwise wij = 0.vi : ( non - spatial overdispersion ( spatial uncorrelated heterogeneity ) ) : by the formulation of the model for spatially correlated heterogeneities , the variance is dependent on the number of neighbors and independence could nt be defined well . in order to justify this problem , another component ( vi ) the prior distribution of this parameter is : vi ~ n ( 0 , v ) 
   : trend component that is overall level of relative risk . ui : ( ( spatial overdispersion ) spatial correlated heterogeneity ) : it is logical that the close areas have similar relative risks . to take this similarities into account , the random variable ui which is uncorrelated with other { uj } sis included in the model . for this component , spatial correlation structure is used where estimates for relative risk in each area are dependent on adjacent areas . the conditional autoregressive model proposed by besag et al . is : if i and j were adjacent , wij = 1 , otherwise wij = 0 . vi : ( non - spatial overdispersion ( spatial uncorrelated heterogeneity ) ) : by the formulation of the model for spatially correlated heterogeneities , the variance is dependent on the number of neighbors and independence could nt be defined well . in order to justify this problem , another component ( vi ) the prior distribution of this parameter is : vi ~ n ( 0 , v ) both u and v parameters control variability of u and v. to analysis of full bayesian , the prior distributions should be determined for these parameters . the first step to evaluate a disease incidence within an area is to estimate the expected rate of incidence in that area . the proportion of observed cases to expected one is called standardized mortality ratio ( smr ) . in studies related to diseases incidence , we use the proportion of observed to expected disease incidence , which is called standardized incidence ratio ( sir ) . this ratio is an estimation of relative risk within each area . in order to utilize this method , the map should be divided into n non - overlapped adjacent areas ( i = 1 , 2 ,  , oi and ei are the number of observed and expected events in i area , respectively . during the study , ei was assumed constant and known and calculated by multiplying the overall crude incidence rate by the area population or its estimation , it is assumed that the number of events between areas are independent and follow poisson distribution with mean eii . therefore , the likelihood for oi is calculated by : also , logarithm of likelihood function is : so , the estimation of maximum likelihood is : although use of smr and sir is so common , there is some substantial shortcoming related to these estimations . to overcome these difficulties , hierarchical bayesian models play an important role in modeling the complexity of data structure in spatial epidemiology and can overcome smrs shortcomings . in addition to observed numbers , bayesian approach in disease mapping contains prior information about geographical variation of disease rates in whole map . it can be also considered disease spatial correlation ( the tendency of nearer areas to the same rates of disease ) . this model assumes that the number of deaths in areas follow a poisson distribution with mean eii . the prior distribution for relative risks is also considered gamma ( a , b ) . to obtain posterior distribution , gamma prior distribution for relative risks is combined with poisson likelihood . so , relative risk have posterior distribution gamma(a + oi , b + ei ) with mean   which . thus , posterior mean for area i is weighted average of smr for area i and overall relative risk that weights are conversely related to smr variance . if the observed and expected counts are high , the estimator tends to smr , but when they are low , it tends to prior mean . the advantages of this method are : 1 . this model estimates full posterior , which allows hypothesis testing and calculates confidence intervals . 2 . even if the real distribution of relative risks is gamma , this model can estimate mean and variance using maximum likelihood method , which is more valuable than moment method . although gamma prior distribution for relative risk is proper from mathematical point of view , it could be limiting because of difficulty with entering covariates . log - normal model is more flexible than gamma- poisson model for relative risks of disease : in this model , vi is included in order to consider spatial correlation and similarity of adjacent areas . this model was introduced by clayton and kaldor and extended by besag , york , and mollie , and its formulation is described as : log(i ) =  + ui + vi in this model , relative risk parameter is splitted into three components : 
  : trend component that is overall level of relative risk.ui : ( ( spatial overdispersion ) spatial correlated heterogeneity ) : it is logical that the close areas have similar relative risks . to take this similarities into account , the random variable ui which is uncorrelated with other { uj } sis included in the model . for this component , spatial correlation structure is used where estimates for relative risk in each area are dependent on adjacent areas . the conditional autoregressive model proposed by besag et al . is : that ,   and if i and j were adjacent , wij = 1 , otherwise wij = 0.vi : ( non - spatial overdispersion ( spatial uncorrelated heterogeneity ) ) : by the formulation of the model for spatially correlated heterogeneities , the variance is dependent on the number of neighbors and independence could nt be defined well . in order to justify this problem , another component ( vi ) the prior distribution of this parameter is : vi ~ n ( 0 , v ) 
   : trend component that is overall level of relative risk . ui : ( ( spatial overdispersion ) spatial correlated heterogeneity ) : it is logical that the close areas have similar relative risks . to take this similarities into account , the random variable ui which is uncorrelated with other { uj } sis included in the model . for this component , spatial correlation structure is used where estimates for relative risk in each area are dependent on adjacent areas . the conditional autoregressive model proposed by besag et al . is : if i and j were adjacent , wij = 1 , otherwise wij = 0 . vi : ( non - spatial overdispersion ( spatial uncorrelated heterogeneity ) ) : by the formulation of the model for spatially correlated heterogeneities , the variance is dependent on the number of neighbors and independence could nt be defined well . in order to justify this problem , another component ( vi ) the prior distribution of this parameter is : vi ~ n ( 0 , v ) both u and v parameters control variability of u and v. to analysis of full bayesian , the prior distributions should be determined for these parameters . the first step to evaluate a disease incidence within an area is to estimate the expected rate of incidence in that area . the proportion of observed cases to expected one is called standardized mortality ratio ( smr ) . in studies related to diseases incidence , we use the proportion of observed to expected disease incidence , which is called standardized incidence ratio ( sir ) . this ratio is an estimation of relative risk within each area . in order to utilize this method , the map should be divided into n non - overlapped adjacent areas ( i = 1 , 2 ,  , oi and ei are the number of observed and expected events in i area , respectively . during the study , ei was assumed constant and known and calculated by multiplying the overall crude incidence rate by the area population or its estimation , it is assumed that the number of events between areas are independent and follow poisson distribution with mean eii . therefore , the likelihood for oi is calculated by : also , logarithm of likelihood function is : so , the estimation of maximum likelihood is : although use of smr and sir is so common , there is some substantial shortcoming related to these estimations . to overcome these difficulties , hierarchical bayesian models play an important role in modeling the complexity of data structure in spatial epidemiology and can overcome smrs shortcomings . in addition to observed numbers , bayesian approach in disease mapping contains prior information about geographical variation of disease rates in whole map . it can be also considered disease spatial correlation ( the tendency of nearer areas to the same rates of disease ) . this model assumes that the number of deaths in areas follow a poisson distribution with mean eii . the prior distribution for relative risks is also considered gamma ( a , b ) . to obtain posterior distribution , gamma prior distribution for relative risks is combined with poisson likelihood . so , relative risk have posterior distribution gamma(a + oi , b + ei ) with mean   which . thus , posterior mean for area i is weighted average of smr for area i and overall relative risk that weights are conversely related to smr variance . if the observed and expected counts are high , the estimator tends to smr , but when they are low , it tends to prior mean . the advantages of this method are : 1 . this model estimates full posterior , which allows hypothesis testing and calculates confidence intervals . 2 . even if the real distribution of relative risks is gamma , this model can estimate mean and variance using maximum likelihood method , which is more valuable than moment method . although gamma prior distribution for relative risk is proper from mathematical point of view , it could be limiting because of difficulty with entering covariates . log - normal model is more flexible than gamma- poisson model for relative risks of disease : in this model , vi is included in order to consider spatial correlation and similarity of adjacent areas . this model was introduced by clayton and kaldor and extended by besag , york , and mollie , and its formulation is described as : log(i ) =  + ui + vi in this model , relative risk parameter is splitted into three components : 
  : trend component that is overall level of relative risk.ui : ( ( spatial overdispersion ) spatial correlated heterogeneity ) : it is logical that the close areas have similar relative risks . to take this similarities into account , the random variable ui which is uncorrelated with other { uj } sis included in the model . for this component , spatial correlation structure is used where estimates for relative risk in each area are dependent on adjacent areas . the conditional autoregressive model proposed by besag et al . is : that ,   and if i and j were adjacent , wij = 1 , otherwise wij = 0.vi : ( non - spatial overdispersion ( spatial uncorrelated heterogeneity ) ) : by the formulation of the model for spatially correlated heterogeneities , the variance is dependent on the number of neighbors and independence could nt be defined well . in order to justify this problem , another component ( vi ) is introduced that is an uncorrelated overdispersion parameter . the prior distribution of this parameter is : vi ~ n ( 0 , v ) 
   : trend component that is overall level of relative risk . ui : ( ( spatial overdispersion ) spatial correlated heterogeneity ) : it is logical that the close areas have similar relative risks . to take this similarities into account , the random variable ui which is uncorrelated with other { uj } sis included in the model . for this component , spatial correlation structure is used where estimates for relative risk in each area are dependent on adjacent areas . the conditional autoregressive model proposed by besag et al . is : if i and j were adjacent , wij = 1 , otherwise wij = 0 . vi : ( non - spatial overdispersion ( spatial uncorrelated heterogeneity ) ) : by the formulation of the model for spatially correlated heterogeneities , the variance is dependent on the number of neighbors and independence could nt be defined well . in order to justify this problem , another component ( vi ) the prior distribution of this parameter is : vi ~ n ( 0 , v ) both u and v parameters control variability of u and v. to analysis of full bayesian , the prior distributions should be determined for these parameters . information about ilam counties population , suicide numbers based on 2006 national census conducted by statistical center of iran and registered suicide cases in each county during 18-month study period from march 2007 till october 2008 is shown in table 1 . population of counties based on national census in year 2006 , the number of suicide cases , and its proportion to each county population , from march 2007 till october 2008 the expected number of suicide cases in each county is calculated by multiplying the provincial crude incidence rate by the county population or its estimation ( third column multiplied by fifth column in table 1 ) . expected number of suicide from march 2007 till october 2008 for estimating relative risk of suicide , at first , estimation based on standardized incidence ratio as classical non - bayesian model was calculated . according to this estimation , the relative risks in counties from highest to lowest ones are dare - shahr ( 2.311 ) , ilam ( 1.158 ) , dehloran ( 1.074 ) , eyvan ( 0.839 ) , abdanan ( 0.677 ) , mehran ( 0.471 ) , shirvan - cherdavel ( 0.302 ) , and malekshahi ( 0.293 ) . then , in order to apply and compare bayesian models in estimating relative risk of suicide in counties of ilam province , dates were fitted to gamma- poisson ( gp ) , log - normal ( ln ) , and full bayesian ( bym ) models by use of winbugs software . estimation of relative risk for suicide in each county was calculated and shown in tables 35 along with standard deviation and confidence interval . using these results , in addition to compare counties relative risks , we can compare three mentioned models . according to estimations made by fitting these models , relative risk estimations of this county using gamma- poisson , log - normal , and bym model were 2.243 , 2.275 , and 2.279 , respectively . estimation relative risk of suicide in ilam counties using gamma - poisson model estimation relative risk of suicide in ilam counties using log - normal model estimation relative risk of suicide in ilam counties using bym model estimation of relative risk for this county based on three mentioned models were 0.321 , 0.321 , and 0.319 respectively that indicates the lower relative risk than expected and the average rate in this province . regarding the confidence intervals resulted from the three models , dare - shahr and ilam counties shown to be significantly higher risk rather than average province ( relative risk more than 1 ) and shirvan - cherdavel , malekshahi , and mehran were found to be lower risk rather than the average amount in the province ( relative risk lower than 1 ) . moreover , the three models were compared by use of dic criterion [ table 6 ] . this criterion is obtained by summing two other criteria , which represents goodness of fit and model complexity respectively . although the estimations obtained from gamma - poisson , log - normal , and bym model represented some differences of standardized incidence ratios according to either amounts and counties incidence ranks , they showed approximately similar estimations for suicide relative risk . these results are in accordance with clayton and kaldor 's findings in comparing bayesian models . they showed that in spite of some differences among relative risk estimations , the ranks for each area are same in all three models . in all three models , the highest standard deviation belonged to dare - shahr county , which has the most number of suicides , and the lowest one was seen in shirvan - cherdavel county with the least ones . one justification for similarities between results of the models could be related to the low number of study areas and registered incidence cases . if the counts in lower levels such as districts or villages are available , their comparisons will be more valuable than recent results . according to the estimations resulted from fitting the models , the ranks of ilam province counties from highest to lowest relative risk of suicide are , in turn : dare - shahr , ilam , dehloran , eyvan , abdanan , mehran , malekshahi , and shirvan - cherdavel . this result is accordance with the only study of geographical variation of suicide incidence in ilam province counties during 1994 - 2001 , which showed that dare - shahr is the highest risk county . . it could be due to different data registry systems , underestimation in various data resources , and the differences in study periods . with regard to the importance of suicide incidence and its remarkable mortality ratio in ilam province , and also for the reason of having various suicide registry systems such as ilam university of medical science , welfare organization , forensic medicine , and the police , it is recommended to conduct more comprehensive survey covering the maximum recorded cases , repeat the study in longer period and in more valuable level of counties like districts or villages . additionally , it 's better to add time term to the study in order to investigate temporal variation along with spatial variation .