 Research article
 Open Access
 Published:
Identifying the determinants and associated factors of mortality under age five in Ethiopia
BMC Public Health volume 21, Article number: 228 (2021)
Abstract
Background
Mortality rate under the age of five is the proportion of deaths of children below the age of 5 years out of 1000 live births. It is related with the living standard of a population, and it is taken as one of the health and socioeconomic status deterioration index. Mortality rate under the age of five also indicates a poor quality life standards of a population. It is very significantly high in SubSaharan African countries. Ethiopia is one of these SubSaharan African countries where mortality rate under the age five is high. This research work aims to identify the determinants and associated factors of underfive mortality in Ethiopia.
Methods
The data for this paper were gathered from the EDHS 2016, collected by CSA. In this study, count family models such as Poisson, negative binomial, zeroinflated Poisson and zeroinflated negative binomial regression were applied for analyzing the data. Each of these count models were compared with different statistical tests like loglikelihood ratio test, Akaike information criteria, mean absolute difference, Vuong test and observed versus predicted probability plot.
Results
The study revealed that as mothers’ age at first birth increased by one unit, the average number of underfive mortality rate decreased by 2.69%. In the same way the number of underfive mortality of Afar, Benishangul Gumuz and Dire Dawa were 1.3446, 1.6429 and 1.3320 times more likely to Tigray respectively. The risk of underfive mortality for primary and secondary education level of the mother was 28.31 and 40.96% less likely than to mothers who have no education respectively.
Conclusion
From the result we found that, there were overabundance zeros and broad heterogeneity in the nonzero outcomes. Zeroinflated negative binomial regression model was found to best fit the data, and from the regression model, age of mothers at first birth, mother’s education level, place of residence and region were statistically significant factors of underfive mortality per mother.
Background
Underfive mortality is related with the prosperity of a population and taken as one of the health and socioeconomic status improvement index and also indicates a quality of life of the population [1]. Decreasing underfive mortality is a global target and it is a Sustainable Development Goals (SDGs) key index. It is targeted to reduce underfive mortality rates below 25 deaths by 2030 [1]. Underfive mortality rate indicates proportion of children deaths occurring between birth and 5 years of age which is expressed out of 1000 live births [2].
Despite the global effort in reducing child mortality over the past few decades, an estimated 5.4 million children under age five died in 2017 [2]. Since 1990, considerable improvements have been made in child survival globally. However, improving child survival stays a matter of critical concern. Among 195 nations, 52 nations need quick progress of diminishing U5M. These nations are found in many parts of the world, and many of them are found in SubSaharan Africa. Among these nations 13 nations will not arrive at the objective until 2050 if existing underfive mortality rate trends go on. The greater number of these deaths are happening in subSaharan Africa. Besides SubSaharan African countries, around 30% are also happening in Southern Asia countries. The SDG goal is targeted to decrease the number of underfive mortality by 10 million between the years 2017 and 2030 [3].
There is a big difference in underfive mortality across the world nations. SubSaharan Africa countries take the greater number of underfive mortality rate on the planet. In 2016, the region had an average underfive mortality rate of 79 deaths for each 1000 live births. This means one child in thirteen deaths before his/her fifth years birthday celebration. It is fifteen times more than the mean proportion of one of every one hundred eighty nine in developed nations, or twenty times more than the proportion of 1 out of 250 in the region of Australia and New Zealand. The danger of death for a child conceived in the most noteworthy mortality nation is around 60 times higher than in the least mortality nation [4].
The Ethiopian Demographic and Health Survey showed 88 and 67 deaths for every 1000 live births in its 2011 and 2016 reports, respectively. The recent UNICEF report indicates that Ethiopia’s underfive mortality rate is 58 per 1000 live births. This figure implies that the underfive mortality rate in the base year 1990 was as high as 206 [1, 5]. Even if underfive mortality has declined in Ethiopia, there is substantial difference among regions of the country [6]. The different regions of the country have diversified lifestyle, culture, ethnic or environmental determinants. Because of the existence of potential cultural, socioeconomic and environmental differences among the population of the country (Tibebu, 2011).
In Ethiopia, the risk of underfive mortality varies by: household income category, level of mother’s education, inadequate access to health services, lack of safe drinking water and sanitation services, poor nutrition and place of residence (MoFED and UNDP, 2012).
Even though there is a research on Poisson and negative binomial regression models such as Tibebu (2011) on multilevel count model, still there is a gap on assessing excess zeros. Hence, underfive mortality is not occurred for all of the women. There is a probability of getting excess zeros, and this situation is solved by fitting zeroinflated Poisson and zeroinflated negative binomial regression models. Therefore, this study is focused on filing this research gap by fitting zeroinflated count statistical regression models of underfive mortality. At the end of the day it is expected to improve the understanding of many people who have the chance of reading the paper on underfive mortality situations in Ethiopia. It also serves as base line information to other researchers for further studies on underfive mortality. The main aim of the study is to identify the determinants and associated factors of under five mortality in Ethiopia.
Methods
Data source
Ethiopian Demographic and Health Survey which was conducted in 2016 by Central Statistical Agency (CSA) was the data source for this paper. The survey was conducted for the fourth time. It covers the rural and urban parts of the nine regions of Ethiopia and the two administrative cities, Dire Dawa and Addis Ababa. The main aim of 2016 Ethiopian Demographic and Health Survey was to present up to date and trusted data on different demographic, environmental, economic, and health related issues [7]. This study analyzed event of 10,283 women aged 15–49 years on the number of underfive mortality that the mother has encountered. The data sets analyzed during the current study are publicly available in the Ethiopian Demographic and Health Survey (EDHS) available at DHS website (http://dhsprogram.com).
Response variable of the study
The number of deaths of children aged from birth up to 59 months that each mother had experienced in her reproductive life time is the variable of interest or the dependent variable (Y_{i}) for this research, and it assumes the values 0, 1, 2, 3, …
Data analysis methods
In research work, it is desirable to align the type of data with an appropriate statistical model. In line with this, count regression models are not similar with normal linear regression models. Hence, count models possess nonnegative discrete and nonlinear values [8]. Poisson regression model is considered as an initial statistical model in count families. So, it fits well with the attribute of count variable [9, 10].
Even though Poisson regression model has an advantage, it has also a potential drawback. Its drawback is an equidispersion of the same mean and variance assumption. When equidispersion assumption is not satisfied, the mean of actual counts is less than the variance, overdispersion takes place. The problem of not controlling overdispersion in the model is that it leads to exaggerated test statistic, unfair standard errors. It also makes the estimates become inconsistent. Usually, it is a common task to overcome the problem of overdispersion after fitting Poisson regression model using either Quasi Likelihood estimation method which is developed by Wedderburn [11] or negative binomial regression model (NBRM) [12, 13].
Negative binomial regression model is an immediate expansion of Poisson regression model, and it can solve overdispersion problem [14, 15]. Moreover, negative binomial regression model estimates the dispersion parameter, and it also specifies the mean and the variance independently [16]. However, in Poisson regression model, the dispersion parameter that connects the variance and the mean set at one. Here we understand that variance is the only dissimilarity between negative binomial and Poisson regression models while the model coefficients can be given to be synonyms across the two specified models. If there is a variability on the variance, it is obvious that the standard errors of the two models are also different. When there is an existence of overdispersion on the response variable, then the variance becomes larger which interne shows that the standard errors are also larger even if it is more proper [17, 18].
The inclusion of dispersion parameter in negative binomial regression model has an advantage of equipping overdispersion by controlling undetected variability in count data. The overdispersion problem arises due to hidden heterogeneity and availability of excess zeros in the data [19]. Even though overdispersion and excess zeros are problems, negative binomial regression model and zero inflated Poisson and zero inflated negative binomial regression models respectively considered as an immediate solutions. In most practical instances, count type of data exhibits the property of rightly skewed, nonnegative, overdispersed and have maximum zeros. Hence, this study furnishes an applied formulation of fitting count data directing on data that possess overdispersion and excess zeroes.
Zeroinflated Poisson and zeroinflated negative binomial regression models
Since there are so many zeros available from the collected data, we applied zeroinflated Poisson and zeroinflated negative binomial regression models to model the collected data [20]. Zeroinflated negative binomial regression model is one of the regression models under the family of count regression models and an extended part of negative binomial regression model [21].
The major difference between zeroinflated Poisson regression model and zeroinflated negative binomial regression model is that just like the replacement of negative binomial regression model by Poisson regression model. Which means a simple adjustment of zeroinflated Poisson regression model gives us zeroinflated negative binomial regression model [22]. The probability mass function is given by:
where λ_{i} is the mean value of the nonzero group and Φ_{i} is the probability of the zero groups of the outcome variable that can be modeled with the related independent variables [23].
The zeroinflated negative binomial regression model has the variance of, var. (y_{i}) = λ_{i} (1Φ_{i}) (1 + αλ_{i} + Φ_{i}λ_{i}) and mean of E (y_{i}) = λ_{i} (1Φ_{i}). The parameters like λ_{i} and Φ_{i} depend on explanatory variables and the value of alpha (α) is a scalar with the value of greater than or equals to zero. Hence, the existence of overdispersion satisfies when either the value of Φ_{i} or α is greater than zero. Thus, the above equation of zeroinflated negative binomial distribution reduced to negative binomial distribution when the parameter Φ_{i} equals zero and in the same way when the value of α becomes zero. Therefore, the above ZINB distribution reduced to zeroinflated Poisson distribution [20].
The likelihood function for estimating the zeroinflated negative binomial regression model parameters are given by [24].
Taking the logarithm of both sides of the likelihood equation and after some adjustment are added, it is given by:
Finally, using EM algorithm we can estimate the unknown parameters of the model.
Model comparisons for underfive mortality
The response variable in this research is the quantity of underfive mortality for every mother in her life time. Such sort of information (data) is modeled using count regression models. In this study, different possible count data models were considered. To distinguish the most proper and well fitted count regression model for the collected data, loglikelihood ratio test, Akaike information criteria, sum of mean absolute difference and Pearson values, Vuong test and observed versus predicted probability plot were used [8, 25–30].
In this study, to choose a best fitting model, four unique statistical models were considered. These are Poisson regression model, negative binomial regression model, zeroinflated Poisson and zeroinflated negative binomial regression models.
Results
Descriptive statistics
The data was analyzed on mothers of reproductive age in the study area. Out of the overall women considered in the sample, 29% of the women in the reproductive age have faced at least one underfive mortality in their lifetimes.
Table 1 indicates that the number and level of underfive mortality that the mothers in the sample have faced in their lifespan. Enormous quantities of underfive mortality for each mother were less often watched, which is strongly skewed to the right with excess zeroes. This is an indication of count data models with excess zeroes may be take into account.
The simple bar chart below displayed as Fig. 1 showed the distribution of the quantity of underfive mortality for each mother. Since the number of zero results are excessively observed, the bar diagram is exceptionally crested at the absolute starting point and it steps down to the right. Generally, it is skewed to the right bar chart. In any case, huge quantities of underfive mortality for every mother were less habitually watched. This perhaps is an indication that count data models with excess zeroes may be take on into account.
Table 2 displayed the general overview of the explanatory variables that directly influence the risk of underfive mortality. The variables which are included in the study are place of residence, region, age at first birth, mass media follow up, education of mother, source of drinking water, availability of toilet facility, wealth index and mother’s religion.
The overall number of mothers considered are 10,283 of which 2978 of them encountered underfive mortality. Generally, 16.73% of urban women faced with the problem of underfive mortality, and it was very small when compared with rural women residents which is 33.39%. The regional variation of underfive mortality per mother occurred the largest in Afar regional state (36.20%) compared with the smallest event in Addis Ababa administrative city (9.90%). All the others are in between the two. Regarding to mass media follow up, the event of underfive mortality was happened to be 18.74% for mothers who follow mass media but for mothers who didn’t develop the habit of following mass media scored 32.92% underfive mortality.
From a theoretical perspective, education of mother is an important determinant factor of underfive survival. Different literatures support this idea. Accordingly, mothers with secondary and above educational level have lowest underfive mortality (10.51%), but mothers who have no educational status have the maximum under five mortality (37.03%).
When we assess drinking water source and sanitation, piped water supply reduces underfive mortality. It reduces especially infant mortality directly by reducing the incidence of diarrhea that arises from the ingestion of contaminated water and food, and indirectly when care givers are able to devote more time to childcare instead of water collection activities. So that, households with piped drinking water source accounted below one over fourth underfive mortality per mother (21.48%) where as households with no piped water source scored 33.40% amount of the event. Large figure of underfive mortality was happened on households without any toilet (33.38%) as compared to households with toilet facility (26.03%).
Previous studies show that wealthier families can provide better nutrition, shelter and health services to children, which lead to an increase in child survival. According to this study among the three wealth index, poor families have largest underfive mortality per mother with the value of 35.05% as compared to rich and middle wealth families.
Goodness of fit of the model and test of Overdispersion
Decency of attack of the fitted Poisson regression model was evaluated using Pearson based Chisquare test. The Pearson goodness of fit test of 10,530.7 at 10260 degree of freedom with pestimation of (p = 0.0302) which would infer solid match for the data. In the event that the Pearson Chisquare worth partitioned by its degree of freedom is somewhat more noteworthy than one, that indicates over dispersion in the data. This result on Table 3, showed that there is a sign of overdispersion. Moreover, it is desirable to apply a formal statistical test of overdispersion. The value of the likelihoodratio test of dispersion parameter alpha was Chisquare = 233.76 with pestimation of < 0.0001 which demonstrated that there is an overdispersion in our data. Moreover, we can use lan of alpha estimation of the proportion test at one which is the chisquare value at one degree of freedom 463.14 with pestimation of < 0.0001 it is significant. Along these lines, the observed data were better clarified by the negative binomial regression model than the Poisson regression model. In accordance with this, the negative binomial regression model was an amended fit than the Poisson regression model as one can see from Table 3, since Akaike information criteria (AIC) (16,121.2) and Bayesian information criterion (BIC) (16,294.92) values are small.
So far existence of overdispersion was assessed. Now it is time to check the cause of overdispersion. It might have happened due to variability of data or extra of zeros. In case of overdispersion, zeroinflated Poisson regression model typically modeled finer than a regular Poisson regression model. At the point when the significant wellspring of overdispersion is a dominance of zero tallies, the subsequent overdispersion cannot be modeled precisely with the negative binomial regression model. An elective path for demonstrating this kind of data is the zeroinflated Poisson or zeroinflated negative binomial regression model which considers the excess of zeroes.
Model selection
As shown in the summery Table 4, we can compare all fitted models based on maximum difference, mean absolute difference, loglikelihood and AIC values. The model with the smallest mean absolute difference and AIC value, at the same time the model with largest maximum difference and likelihood ratio is preferred. When we see the absolute mean difference, ZINB model is preferred, because it has smallest mean absolute difference value. In other words, by considering AIC value, ZINB is also preferable. Since ZINB has largest loglikelihood value and maximum difference, in line with this ZINB model is the most appropriate and preferable model among the four models.
For nonnested models as shown on Table 5: ZIP versus Poisson and ZINB versus NB regression models were identified using the Vuong test statistic. At the same time, for nested models which is displayed on Table 6, Poisson versus NB and ZIP versus ZINB regression models could be identified by using likelihoods ratio test.
Table 7 indicates that we have actual or observed values, predicted probability, absolute difference between actual and predicted probability values and Pearson values of the four count models. When we observe the sum of mean absolute difference, ZINB model had the minimum values from the other three models. In addition to this; among the four models, the one which has the smallest sum of Pearson value is the best model. From the table, ZINB has the minimum Pearson sum of the predicted and actual probabilities than other count models. However, negative binomial regression model seems to have the smallest Pearson sum and mean absolute difference but it doesn’t perform as much as ZINB regression model done. This might be an indication of there is improvement in ZINB regression model than negative binomial regression model.
In addition, the model would be compared by using observed versus predicted probability plot. Hence, the residual plot in Fig. 2 confirms that ZINB model fits well the data and it is the most appropriate model among the four count models because almost all ZINB points pass through 0 and makes a straight line after some moments of underfive mortality and if we compare the models on the graph ZINB regression model best approaches the zero line.
Discussion
The finding of the study for nonzero group at Table 8 showed that, age of mothers at first birth was found to be a significant factor on underfive mortality. By keeping other variables held constant in the model, a one unit increase of age at first birth will decrease the average number of underfive mortality by 2.69% in Ethiopia (IRR = 0.9731; CI = 0.9638, 0.9825). With regard to region, the number of underfive mortality per mother has risk for those mothers who live in Afar, Benishangul Gumuz regional state and Dire Dawa city administration. The risk of underfive mortality for those mothers who live in Afar regional state was 1.3446 (IRR = 1.3446; CI = 1.0514, 1.7196) times more likely to die before age five as compared to those mothers who lives in Tigray regional state keeping other variables held constant in the model. Similarly, by keeping other variables held constant in the model, the risk of underfive mortality for those mothers who live in Benishangul Gumuz regional state was 1.6429 (IRR = 1.6429; CI = 1.2891, 2.0938) times more likely to die before age five as compared to those mothers who live in Tigray regional state. In the same way, mothers who live in Dire Dawa city administration was 1.3320 (IRR = 1.3320; CI = 1.0136, 1.7505) times more likely to die before age five as compared to those mothers who live in Tigray regional state keeping other variables held constant in the model. According to the result of this study, mother’s education level was found to be statistically significant factor for underfive mortality in Ethiopia. The result indicates that the risk of underfive mortality was 28.31% (IRR = 0.7169; CI = 0.6552, 0.7844) less likely for mothers who has primary education level as compared to mothers who have no education level keeping other variables held constant in the model. Similarly, the risk of under five mortality was 40.96% (IRR = 0.5904; CI = 0.4940, 0.7056) less likely for mothers who has secondary and above education level as compared to mothers who have no education level keeping other variable held constant in the model.
The result of this study for inflated group as displayed on Table 9, showed that place of residence was found to be statistically significant factor for underfive mortality in Ethiopia. By keeping other variables held constant in the model, the risk of underfive mortality was 44.03% (OR = 0.5597; CI = 0.3379, 0.9272) times less than for mothers who live in rural part of Ethiopia as compared to mothers who live in urban part of Ethiopia. The finding of this study showed that the number of underfive mortality per mother has risk for those mothers who live in Benishangul Gumuz regional state. By keeping other variables held constant in the model, the risk of underfive mortality those mothers live in Benishangul Gumuz regional state was 2.7008 (OR = 2.7008; CI = 1.1008, 6.6261) times greater than those mothers who lives in Tigray regional state.
Conclusions
This study was designed to identify the most important underfive mortality variables through count regression models in Ethiopia. The study also identifies the best count fit model in order to analyze underfive mortality data. The data were taken from [7] Ethiopian Demographic and Health Survey data. In this study, 10,283 women were taken, out of which 71% of the mothers have not faced any underfive mortality in their lifetime. This implies that using zero inflated model is appropriate to fit this data set. From the exploratory results we could identify that there is an excess zeros and high variability in the nonzero values. The variance of the number of underfive mortality was larger than its mean, indicating that there was possibility of overdispersion.
The appropriate fitted model was selected from among different candidate models like Poisson, negative binomial (NB), zeroinflated Poisson (ZIP) and zeroinflated negative binomial (ZINB) regression models using different comparison techniques. The comparison was conducted through loglikelihood ratio test (LRT), Akaike information criteria (AIC), mean absolute difference, Vuong test and observed versus predicted probability plot. LRT which is used to compare any two nested models such as Poisson versus negative binomial (NB) and zeroinflated Poisson (ZIP) versus zeroinflated negative binomial (ZINB) was used. Nonnested models such as Poisson versus ZIP and NB versus ZINB were compared using Vuong test.
Since the underfive mortality data in Ethiopia contains an excess zero, the standard Poisson and negative binomial regression models were not enough to fit the data well. Zeroinflated negative binomial model was appropriate to fit the number of underfive mortality data due to the presence of excess zero in the data. In addition to this, the violation of Poisson model assumption that is the mean is smaller than the variance of number of underfive mortality.
This study also involves predictor variables that had significant effects on number of underfive mortality per mother in Ethiopia. For selected ZINB model, for the nonzero group, the predictor variables like age of mothers at first birth, region, mother’s education level were statistically significant factors while for the zero group, place of residence and region were statistically significant factor on the number of underfive mortality per mother in Ethiopia.
Limitation of the study
Some variables were not included in the study due to the presence of high missing values such as: number of antenatal visits for pregnancy, preceding birth interval, smoking cigarettes, duration of breastfeeding, chewing chat etc. Since this study was based on secondary data from EDHS 2016, we try to study only the variables which are included in the questionnaire. In addition, the study used reported characteristics of mothers and households that may vary with time. Mothers’ age at first birth was fixed but others are timevarying covariates. However, in this analysis, all covariates were considered as fixed during the study period. Moreover, only surviving women age 15–49 were interviewed. Therefore, no data were available for children of women who had died.
Availability of data and materials
All the data are publicly accessible on Ethiopian Demographic and Health Survey (EDHS) available at DHS website (http://dhsprogram.com).
Abbreviations
 AIC:

Akaike Information Criteria
 BIC:

Bayesian Information Criterion
 EDHS:

Ethiopian Demographic and Health Survey
 HIV:

Human Immune Virus
 AIDS:

Accrued Immune Deficiency syndrome
 LRT:

Likelihood Ratio Test
 NBRM:

Negative Binomial Regression Model
 PRM:

Poison Regression Model
 SDGs:

Sustainable Development Goals
 U5M:

UnderFive Mortality
 ZINB:

Zeroinflated Negative Binomial Regression
 ZIP:

ZeroInflated Poisson
 CSA:

Central Statistical Agency
References
 1.
United Nations. Department of Economic and Social Affairs Population Division. World Mortality 2017: Data Booklet. New York: United Nations; 2017.
 2.
Hug L, Dharrow D, Zhong K, You D. Levels and trends in child mortality: Report 2018: The World Bank; 2018. (No. 129971, pp. 148)
 3.
World Health Organization, 2018. Monitoring Health for the Sustainable Development Goals, Geneva.
 4.
United Nations Interagency Group for Child Mortality Estimation. Levels and Trends in Child Mortality report estimates. New York: United Nations Children’s Fund; 2017.
 5.
Wardlaw T, You D, Hug L, Amouzou A, Newby H. UNICEF Report: enormous progress in child survival but greater focus on newborns urgently needed. Reproductive health. 2014;11(1):1–4.
 6.
Getiye TIBEBU. Identification of risk factors and regional differentials in under five mortality in Ethiopia using multilevel count model (Doctoral dissertation, M. Sc. Thesis, Addis Ababa University, Addis Ababa); 2011.
 7.
Csa I. Central statistical agency (CSA)[Ethiopia] and ICF. Ethiopia demographic and health survey, Addis Ababa, Ethiopia and Calverton, Maryland, USA; 2016.
 8.
Karlaftis MG, Tarko AP. Heterogeneity Considerations in Accident Modeling. Accident Analysis and Prevention. 1998;30(4):425–33.
 9.
Shankar VN, Mannering F, Barfield W. Effect of Roadway Geometric and Environmental Factors on Rural Freeway Accident Frequencies. Accident Analysis and Prevention. 1995;27(3):371–89.
 10.
Yaacob WFW, Lazim AM, Wah BY. A Practical Approach in Modeling Count Data: Proceedings of the Regional Conference on Statistical Sciences (RCSS’10), 176183; 2010.
 11.
Wedderburn RWM. Quasilikelihood functions, generalized linear models and the Gauss–Newton method. Biometrika. 1974;61:439–47.
 12.
Agresti A. Categorical Data Analysis. New York: Wiley Interscience; 2002.
 13.
Cameron AC, Trivedi PK. Micro econometrics Methods and Application: Cambridge University Press; 2005.
 14.
Cox DR. Some Remarks on Overdispersion. Biometrika. 1983;70:269–74.
 15.
Lawless JF. Negative binomial and mixed Poisson regression. Canadian Journal of Statistics. 1987;15(3):209–25.
 16.
Heilborn, D.C., 1989. Generalized linear models for altered zero probabilities and overdispersion in count data. Unpublished Technical report, University of California, San Francisco, Department of Epidemiology and Biostatistics.
 17.
Guevara FL, Washington SP. Forecasting Crashes at the Planning Level Simultaneous Negative Binomial Crash Model Applied in Tucson, Arizona. In: Transportation Research Record: Journal of the Transportation Research Board, No.1897. Washington, D.C.: TRB, National Research Council; 2004. p. 491–9.
 18.
McCarthy PS. Public Policy and Alcohol Related Crashes among Old Driver; 2005.
 19.
Dejen T, Muniswamy. Power of Tests for Negative Binomial Regression Coefficients in Count Data. International Journal of Mathematical Archive. 2012;3(8):3136–42.
 20.
Lambert D. Zeroinflated Poisson regression, with an application to defects in manufacturing. Technometrics. 1992;34:1–14.
 21.
Long JS, Freese J. Regression models for categorical dependent variables using stata 2nd edn. College Station TX: Stata Press; 2006.
 22.
Sarkisian N, Gerstel N. Explaining the Gender Gap in Help to Parents: The Importance of Employment. Journal of Marriage and the Family. 2004;66:431–51.
 23.
Zuur FA, Ieno NE, Walker NJ, Saveliev AA, Smith MG. Mixed effects Models and Extensions in Ecology with R. New York: Springer; 2009.
 24.
Yau Z., 2006. Score Tests for Generalization and ZoreInflation in Count Data Modeling. Unpublished Ph. D. Dissertation, University of South Caroline, Columbia.
 25.
Akaike H. In: Petrov BN, Csaki F, editors. Information theory and extension of the maximum likelihood principle, Second international Symposium on Information Theory. Budapest: Academia Kiado; 1973. p. 267–81.
 26.
Bauer L, Greibe P, Hua L, Liang L. Statistical Models of Accidents on interchange ramps and speed change lines. FHWA RD – 97106, U.S: Department of Transportation; 2007.
 27.
Lee AH, Xiang L, Fung WK. Sensitivity of score test for zeroinflation in count data. Statistics in Medicine. 2004;23:2757–69.
 28.
Miaou S p. The relationship between truck accidents and geometric design of road sections: Poisson versus Negative binomial regressions. Accident Analysis and Prevention. 1994;26:471–82.
 29.
Van den Broek J. A score test for zero inflation in Poisson distribution. Biometrics. 1995;51:738–43.
 30.
Vuong QH. Likelihood ratio tests for model selection and nonnested hypotheses. Econometrica. 1989;57:307–33.
Acknowledgements
Not applicable.
Funding
This research did not receive any specific funding.
Author information
Affiliations
Contributions
H. K.Y. contributed in the conceptualization of the research problem, study design, analysis of the data, interpretation of the final result and formulate the manuscript; M. Z. F. participated in, revision of the research, data analysis and editing of the manuscript and H. G. G. contributed in guidance, consultation and continued follow up and encouragement from the beginning to the end of the study and revision of the thesis. Each and every authors of the paper carefully read, edited and finally approved the final manuscript.
Corresponding author
Ethics declarations
Ethics approval and consent to participate
The study was based on publicly available data from the EDHS. Ethical approval was the responsibility of the agency which collected the data.
Consent for publication
Not applicable.
Competing interests
All authors declare no competing interest.
Additional information
Publisher’s Note
Springer Nature remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.
Rights and permissions
Open Access This article is licensed under a Creative Commons Attribution 4.0 International License, which permits use, sharing, adaptation, distribution and reproduction in any medium or format, as long as you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons licence, and indicate if changes were made. The images or other third party material in this article are included in the article's Creative Commons licence, unless indicated otherwise in a credit line to the material. If material is not included in the article's Creative Commons licence and your intended use is not permitted by statutory regulation or exceeds the permitted use, you will need to obtain permission directly from the copyright holder. To view a copy of this licence, visit http://creativecommons.org/licenses/by/4.0/. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated in a credit line to the data.
About this article
Cite this article
Yohannis, H.K., Fetene, M.Z. & Gebresilassie, H.G. Identifying the determinants and associated factors of mortality under age five in Ethiopia. BMC Public Health 21, 228 (2021). https://doi.org/10.1186/s12889021101575
Received:
Accepted:
Published:
Keywords
 Underfive mortality
 Count regression models
 Overdispersion
 Ethiopia