# The Generalization Inverse Weibull Distribution Related to X-Gamma Generator Family: Simulation and Application for Breast Cancer

Authors: R. Alshenawy
Journal: Journal of Function Spaces
 (2022)

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## Abstract

The aim of this paper is to propose the new three-parameter X-Gamma inverse Weibull (XGAIW) distribution which generalizes the inverse Weibull model. The density function of the XGAIW can be expressed as a linear combination of the inverse Weibull densities. Some mathematical quantities (reliability and hazard rate properties) of the proposed XGAIW model are derived. Moreover, four estimation methods, namely, the maximum likelihood, maximum product spacing, least squares, and weighted least squares methods, are utilized to estimate the XGAIW parameters. The Monte Carlo simulation study has been performed to assess the performance of the proposed estimation methods using some criteria. The importance, flexibility, and potentiality of the XGAIW model are studied via a breast cancer data set application. The XGAIW model can produce better fits than some well-known distributions, so the proposed model can be used, as a good alternative to some existing distributions, in modeling several real data.


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## Body

## 1. Introduction

In statistics literature, many new families of lifetime distributions are developed and commonly used to describe real-world phenomena. It is well known that adding an extra parameter to an existing family of distributions is very common in the statistical distribution theory. Often introducing an extra parameter brings additional flexibility to a class of probability distributions, and, in turn, it can be very useful for data analysis purposes. A common feature of these new classes of distributions is that they have more parameters and the model adequacy of the new generalized distribution performs better than the baseline distribution. Therefore, introducing new probability distributions and/or extending (or generalizing) existing probability distributions by adding extra parameters into its form has become a time-honored device for obtaining more flexible new families of distribution; see Alshenawy [1].Inverse (or inverted) distributions are significant in many fields, including biological sciences, life test problems, and medical sciences, because of their applicability. Inverted conformation distributions have a different structure than noninverted conformation distributions in terms of density and hazard ratio. The inverse Weibull (IW) distribution is an important probability distribution which can be used to analyze the lifetime data with some monotone failure rates. It is a suitable model to describe degradation phenomena of mechanical components as mentioned by Keller et al. [2] and Alkarni et al. [3]. According to Nelson [4], the IW distribution provides a good fit to several data sets such as the times to breakdown of an insulating fluid subject to the action of a constant tension. The IW distribution has been used to model many real-life applications including medicine, reliability, and ecology. Some useful measures for the IW distribution have been discussed by Jiang et al. [5]. The IW distribution is appropriate model to a variety of failure characteristics such as wear-out period, infant mortality, and useful life; see Khan et al. [6], Hassan and Nassr [7], Subhradev [8], Khan and King [9], Biçer [10], and Ahmad and Almetwally [11].Calabria and Pulcini [12] computed the maximum likelihood and least squares estimate of the parameters of the IW distribution. They also obtained the Bayes estimator of the model parameters as well as confidence limits for reliability and tolerance limits. See Calabria and Pulcini [13] for additional details. The random variable x has an IW distribution if its cumulative distribution function (CDF) takes the form
(1)GIWx;α,β=e−αx−β;x≥0,α,β>0,where α and β are the scale and shape parameters, respectively. If α=1, we have the Fréchet distribution function. The corresponding probability density function (PDF) is given by
(2)gIWx;α,β=αβx−β−1e−αx−β;x≥0,α,β>0.Ifβ=1, the IW (PDF) becomes inverse exponential (PDF), and when β=2, the IW (PDF) is referred to as the inverse Raleigh (PDF).The quantile function isQFx=−lnu/α−1/β;0<u<1. In addition to that, the IW (PDF) satisfies
(3)xfx;α,β=βFx;α,β−lnFx;α,β;x≥0,α,β>0.In recent years, many generalized classes of distributions have been proposed for modeling real-life data to provide great flexibility in modelling data in several applied fields such as reliability, engineering, biological studies, economics, medical sciences, environmental sciences, and finance. For example, Jiang et al. [14] presented the Weibull and Weibull inverse mixture models. Sultan et al. [15] discussed the mixture of two IW distributions. Khan et al. [6] studied the flexibility of the IW distribution. De Gusmao et al. [16] proposed the generalized IW distribution and discussed several properties of this model with applications. Hemmati et al. [17] proposed the three-parameter Weibull-Poisson distribution as an aging class distribution. Khan et al. [18] proposed the new class of transmuted inverse Weibull distribution with application to reliability data. Baharith et al. [19] introduced the beta generalized inverse Weibull distribution. Finally, Kamel and Alqarni [20] proposed a new characterization of exponential distribution through minimum chi-squared divergence principle with some illustrative examples.Additionally, the X-Gamma (XG) distribution is introduced by Sen et al. [21] and Sen et al. [22] as the probability distribution model with a single shape parameter. The XG distribution, which has many useful statistical features, is a probability distribution that could have the potential use for the modeling of lifetime data from a wide range of the field of science. Sen et al. [21] have studied many useful features of XG distribution. Although it has nice statistical properties, it is a disadvantage of XG that the distribution has only one parameter which plays a crucial role in determining the various behaviors of the distribution. Until today, various attempts have been made by several researchers to eliminate this disadvantage of the distribution. However, the XG distribution needs to be improved in an aspect of the ability to a model for a wide variety of data types especially the data with the hazard rates in different forms. Sen et al. [23] studied discrimination analysis between the Lindley and XG distribution. Finally, Yadav et al. [24] introduced inverse XG distribution using the transformation Y=1/XMoreover, the XG-Generator (XG-G) family has been proposed by Cordeiro et al. [25] to incorporate any distribution into a larger family through an application of the XG (CDF). Based on the T–X transform defined by Alzaatreh et al. [26] and the XG (CDF), the XG-G family has flexible shapes to model various lifetime data sets. Additionally, its special models produce better fits than other well-known families. The XG-G family added a parameter which has one extra shape parameter λ>0, and the CDF of XG-G family is given by
(4)Fx;λ,γ=1−1−Gx;γλλ+11+λ−λln1−Gx;γ+0.5λ2ln1−Gx;γ2,where Gx;γ is a baseline CDF with a parameter vector γ. The PDF of XG-G family can be expressed as
(5)fx;λ,γ=λλ+1gx;γ1−Gx;γλ−1λ0.5λ2ln1−Gx;γ2,wheregx;γ=dGx;γ/dx.We are motivated to introduce the new generalized inverse Weibull distribution because of the above generalizations in the exponentiated family of lifetime distributions. This paper introduces a new three parameter distribution called the X-Gamma inverse Weibull (XGAIW) distribution based on the XG-G family, which contains some lifetime distributions as special submodels. Also, this paper deliberates the comprehensive description of mathematical properties of the new model and presents a graphical analysis of some of its properties. We study different classical point estimation methods for the unknown parameters of XGAIW distribution. Some properties of the density function are discussed. Numerical methods are used to solve the obtained nonlinear equations. Simulation study is used to make comparison between those methods and also to determine which method is more efficient according to the Bias and mean square error (MSE) criteria. The proposed model can be used, as a good alternative to some existing distributions, in modeling several real data.The rest of the paper is organized as follows. In Section2, we define the XGAIW distribution and derive a useful representation for its PDF. The mathematical quantities (reliability and hazard rate properties) of the XGAIW distribution are derived in Section 3. In Section 4, the XGAIW parameters are estimated via four methods, namely, the maximum likelihood, maximum product spacing, least squares, and weighted least squares estimators. These estimators are compared via some simulations in Section 5. In Section 6, we illustrate the flexibility and potentiality of the XGAIW model using a real data set. Finally, some concluding remarks are offered in Section 7.


## 2. The XGAIW Distribution

In this section, we will introduce the XGAIW distribution and some of its submodels. The XG-G family and IW distribution have been used to generate XGAIW distribution. It is represented by the random variableX~XGAIWλ,α,β. By using Equations (1)–(4), the CDF of the three-parameter XGAIW distribution takes this form:
(6)Fx;λ,α,β=1−1−e−αx−βλλ+11+λ−λln1−e−αx−β+0.5λ2ln1−e−αx−β2,where λ,α,β>0 and x>0. The corresponding PDF of XGAIW distribution is given as
(7)fx;λ,α,β=λαβλ+1x−β−1e−αx−β1−e−αx−βλ−1λ+0.5λ2ln1−e−αx−β2.The plots of density function are displayed in Figure1. This figure provides some shapes of the PDF of the XGAIW distribution for some different values of the parameters.Figure 1
Plots of the PDF of the XGAIW distribution for different values of parameters.The XGAIW distribution with three parametersλ,α,β with PDF in Equation (7) is a very flexible model that approaches to different distributions as special submodels:
(1)
Ifα⟶1, then PDF in Equation (7) reduces to the two-parameter distribution, this is a new model, which can be denoted as X-Gamma inverse exponential (XGAIE) distribution(2)
Ifα⟶2, then PDF in Equation (7) reduces to the two-parameter distribution, this is a new model, which can be denoted as X-Gamma inverse Rayleigh (XGAIR) distribution


## 3. Reliability Analysis

The reliability function (survival function) of XGAIW distribution is given by(8)Sx;λ,α,β=1−e−αx−βλλ+11+λ−λln1−e−αx−β+0.5λ2ln1−e−αx−β2.The hazard rate function (failure rate) of a lifetime random variableX with XGAIW distribution is given by
(9)hx;λ,α,β=λαβx−β−1e−αx−βλ+0.5λ2ln1−e−αx−β21−e−αx−β1+λ−λln1−e−αx−β+0.5λ2ln1−e−αx−β2.Figure2 displays plots of the hazard rate function (HRF) of the XGAIW distribution for some values of the parameters as follows.Figure 2
Plots of the HRF of the XGAIW distribution for different values of parameters.


## 4. Estimation Methods for XGAIW Distribution

In this section, the parameter estimation of the XGAIW parameters is investigated using four methods of estimation, namely, the maximum likelihood estimators (MLEs), maximum product spacing estimators (MPSEs), least squares estimators (LSEs), and weighted least squares estimators (WLSEs), in the presence of complete sample which will be discussed in details.


### 4.1. Maximum Likelihood Estimators

We determine the MLEs of the XGAIW parameters. Letx1,x2,⋯,xn be a random sample of size n from XGAIW δ where δ=λ,α,βT. The log-likelihood function for δ of XGAIW distribution is given by
(10)ℓλ,α,β=nlnλλ+1+nlnβ+lnα−β+1∑i=1nlnxi−α∑i=1nxi−β+λ−1∑i=1nln1−e−αxi−β+∑i=1nlnλ+0.5λ2ln1−e−αxi−β2.We can maximize the above log-likelihood equation by solving the nonlinear likelihood equations, which follow by differentiating it. Further, the resulting equations cannot be solved analytically, so some softwares can be used to solve them numerically via iterative techniques such as a Newton–Raphson algorithm. The associated components of the score vector(11)Unδ=∂l∂λ,∂ℓ∂α,∂ℓ∂βTare given by
(12)∂ℓ∂λ=nλλ+1+∑i=1nln1−e−αxi−β+∑i=1n1+λln1−e−αxi−β2λ+0.5λ2ln1−e−αxi−β2,∂ℓ∂α=nα+∑i=1nxi−β+λ−1∑i=1ne−αxi−βxi−β1−e−αxi−β+λ2∑i=1nln1−e−αxi−βe−αxi−βxi−β/1−e−αxi−βλ+0.5λ2ln1−e−αxi−β2,∂ℓ∂β=nβ−∑i=1nlnxi+α∑i=1nxi−βlnxi−λ−1α∑i=1ne−αxi−βlnxi1−e−αxi−β−λ2∑i=1nln1−e−αxi−βe−αxi−βlnxi/1−e−αxi−βλ+0.5λ2ln1−e−αxi−β2.


### 4.2. Maximum Product Spacing Estimators

In statistics, the maximum product spacing estimator (MPSE) is a method for estimating the parameters of univariate statistical models. The method requires maximization of the geometric mean of spacings in the data, which are the differences between the values of the cumulative distribution function at neighboring data points. One of the most common methods for estimating the parameters of a distribution from data, the method of MLEs, can break down in various cases, such as involving certain mixtures of continuous distributions. In these cases, the MPSE method may be successful. The MPS method chooses the parameter values that make the observed data as uniform as possible, according to a specific quantitative measure of uniformity.According to Cheng and Amin [27] and Alshenawy et al. [28] MPSE was introduced, and the uniform spacings of a random sample x1<⋯<xn of size n from the XGAIW distribution can be defined by
(13)Diλ,α,β=Fxi,λ,α,β−Fxi−1,λ,α,β;i=1,2,⋯,n+1,where Di refers to the uniform spacings and ∑i=1n+1Di=1. The MPSEs can be obtained by maximizing
(14)Gλ,α,β=1n+1∑i=1n+1lnDiλ,α,β.The natural logarithm of the product spacing function for the MPSEs of XGAIW distribution is given by(15)lnGλ,α,β=1n+1lnbλ,ψxn,β,α+ln1−bλ,ψx1,β,α+∑i=2nlnbλ,ψxi−1,β,α−bλ,ψxi,β,α,where ψxi;β,α=1−e−αxi−β,bλ,ψ=ψλ/λ1+λ−λlnψ+0.5λ2lnψ2.To obtain the normal equations for the unknown parameters, we differentiate partially Equation (15) with respect to the vector parameter δ and equate them to zero. The estimators of δ can be obtained by solving the system of nonlinear equations, so the MPSEs of λ, α, and β can be found by using any iterative procedure technique such as conjugate-gradient algorithm solution.


### 4.3. Ordinary and Weighted Least Squares

Swain et al. [29] introduced the LSE and WLSE methods that are used to estimate the parameters of beta distribution. Let x1<x2<⋯<xn be the order statistics of a sample from the XGAIW distribution, and then, the LSEs and WLSEs of λ, α, and β can be obtained by minimizing the following function with respect to λ, α, and β:
(16)Sλ,α,β=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+12,where (Ai=1) in the case of LSEs and Ai=n+12n+2/in−i+1 in the case of WLSEs. Further, the LSEs and WLSEs of the XGAIW parameters are also obtained by solving the following nonlinear equations simultaneously with respect to λ, α, and β:
(17)∂Sλ,α,β∂λ=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+1φ1i=0,∂Sλ,α,β∂α=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+1φ2i=0,∂Sλ,α,β∂β=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+1φ3i=0,where
(18)φ1i=−ϕi2λ+11−lnϕi+λlnϕi2+1λ+11−λ+1lnϕi1+λ−λlnϕi+λlnϕi2,φ2i=λ+0.5λ2lnϕi2−λxi−βϕiλ−11−ϕiλ+1,φ3i=λ+0.5λ2lnϕi2−λlnxiϕiλ−11−ϕiλ+1,ϕi=1−e−αxi−β.


## 4.1. Maximum Likelihood Estimators

We determine the MLEs of the XGAIW parameters. Letx1,x2,⋯,xn be a random sample of size n from XGAIW δ where δ=λ,α,βT. The log-likelihood function for δ of XGAIW distribution is given by
(10)ℓλ,α,β=nlnλλ+1+nlnβ+lnα−β+1∑i=1nlnxi−α∑i=1nxi−β+λ−1∑i=1nln1−e−αxi−β+∑i=1nlnλ+0.5λ2ln1−e−αxi−β2.We can maximize the above log-likelihood equation by solving the nonlinear likelihood equations, which follow by differentiating it. Further, the resulting equations cannot be solved analytically, so some softwares can be used to solve them numerically via iterative techniques such as a Newton–Raphson algorithm. The associated components of the score vector(11)Unδ=∂l∂λ,∂ℓ∂α,∂ℓ∂βTare given by
(12)∂ℓ∂λ=nλλ+1+∑i=1nln1−e−αxi−β+∑i=1n1+λln1−e−αxi−β2λ+0.5λ2ln1−e−αxi−β2,∂ℓ∂α=nα+∑i=1nxi−β+λ−1∑i=1ne−αxi−βxi−β1−e−αxi−β+λ2∑i=1nln1−e−αxi−βe−αxi−βxi−β/1−e−αxi−βλ+0.5λ2ln1−e−αxi−β2,∂ℓ∂β=nβ−∑i=1nlnxi+α∑i=1nxi−βlnxi−λ−1α∑i=1ne−αxi−βlnxi1−e−αxi−β−λ2∑i=1nln1−e−αxi−βe−αxi−βlnxi/1−e−αxi−βλ+0.5λ2ln1−e−αxi−β2.


## 4.2. Maximum Product Spacing Estimators

In statistics, the maximum product spacing estimator (MPSE) is a method for estimating the parameters of univariate statistical models. The method requires maximization of the geometric mean of spacings in the data, which are the differences between the values of the cumulative distribution function at neighboring data points. One of the most common methods for estimating the parameters of a distribution from data, the method of MLEs, can break down in various cases, such as involving certain mixtures of continuous distributions. In these cases, the MPSE method may be successful. The MPS method chooses the parameter values that make the observed data as uniform as possible, according to a specific quantitative measure of uniformity.According to Cheng and Amin [27] and Alshenawy et al. [28] MPSE was introduced, and the uniform spacings of a random sample x1<⋯<xn of size n from the XGAIW distribution can be defined by
(13)Diλ,α,β=Fxi,λ,α,β−Fxi−1,λ,α,β;i=1,2,⋯,n+1,where Di refers to the uniform spacings and ∑i=1n+1Di=1. The MPSEs can be obtained by maximizing
(14)Gλ,α,β=1n+1∑i=1n+1lnDiλ,α,β.The natural logarithm of the product spacing function for the MPSEs of XGAIW distribution is given by(15)lnGλ,α,β=1n+1lnbλ,ψxn,β,α+ln1−bλ,ψx1,β,α+∑i=2nlnbλ,ψxi−1,β,α−bλ,ψxi,β,α,where ψxi;β,α=1−e−αxi−β,bλ,ψ=ψλ/λ1+λ−λlnψ+0.5λ2lnψ2.To obtain the normal equations for the unknown parameters, we differentiate partially Equation (15) with respect to the vector parameter δ and equate them to zero. The estimators of δ can be obtained by solving the system of nonlinear equations, so the MPSEs of λ, α, and β can be found by using any iterative procedure technique such as conjugate-gradient algorithm solution.


## 4.3. Ordinary and Weighted Least Squares

Swain et al. [29] introduced the LSE and WLSE methods that are used to estimate the parameters of beta distribution. Let x1<x2<⋯<xn be the order statistics of a sample from the XGAIW distribution, and then, the LSEs and WLSEs of λ, α, and β can be obtained by minimizing the following function with respect to λ, α, and β:
(16)Sλ,α,β=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+12,where (Ai=1) in the case of LSEs and Ai=n+12n+2/in−i+1 in the case of WLSEs. Further, the LSEs and WLSEs of the XGAIW parameters are also obtained by solving the following nonlinear equations simultaneously with respect to λ, α, and β:
(17)∂Sλ,α,β∂λ=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+1φ1i=0,∂Sλ,α,β∂α=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+1φ2i=0,∂Sλ,α,β∂β=∑i=1nAi1−1−e−αxi−βλλ+11+λ−λln1−e−αxi−β+0.5λ2ln1−e−αxi−β2−in+1φ3i=0,where
(18)φ1i=−ϕi2λ+11−lnϕi+λlnϕi2+1λ+11−λ+1lnϕi1+λ−λlnϕi+λlnϕi2,φ2i=λ+0.5λ2lnϕi2−λxi−βϕiλ−11−ϕiλ+1,φ3i=λ+0.5λ2lnϕi2−λlnxiϕiλ−11−ϕiλ+1,ϕi=1−e−αxi−β.


## 5. Monte Carlo Simulation Study

In this section, we conduct a Monte Carlo simulation study to estimate the parameters based on complete sample by using MLE, MPSE, LSE, and WLSE methods. R software is used to perform our Monte Carlo simulation study; see Alshenawy et al. [30].Monte Carlo experiments were carried out based on 10,000 random samples for following data generated form XGAIW distribution by using numerical analysis, wherexi is distributed as XGAIW distribution for different parameters λ,α,β with different actual values of parameter and for different sample sizes n=50,100,and150. We compare the performances of the MLE, MPSE, LSE, and WLSE methods based on the Bias and mean squared errors (MSE) for different sample sizes. Therefore, we report all the results up to three decimal places. Remember that Bias estimator is Bias=δ^−δ, where δ is the estimated value of δ, and the MSE of the estimator is MSE=Meanδ∧−δ2.We conclude remarks on the Monte Carlo simulation study as follows:(1)
The simulation outcomes are recorded in Tables1–5. The following concluding remarks are noticed based on these tables as follows(2)
The Bias and MSE values ofα, β, and λ for all estimation methods decrease as the sample size n increases(3)
The MPSE method has more relative efficiency than MLEs for most parameters of XGAIW distribution in all tables(4)
We can analyze that by increasingα, the MSE and Bias for the parameter β decrease while for λ decrease, in most cases(5)
The LSEs have the lowest MSE in most cases ofα and β. Also, the WLSEs have the least MSE in most cases of λ for different sample sizesTable 1
Bias and MSE values forα, β, and λ of the XGAIW distribution.
ParametersMLEsMPSEsLSEsWLSEsBiasMSEBiasMSEBiasMSEBiasMSEn=50α=0.50.43770.44230.44330.25230.36430.23420.43210.2274β=0.50.68760.83520.43890.31420.33090.15640.31840.1322λ=1-0.07980.15190.16920.14300.06980.13860.03710.1163n=100α=0.50.43660.33680.39370.17260.36200.17090.39840.1604β=0.50.45630.37280.39270.28470.35170.13820.35820.1488λ=1-0.02260.06930.04630.06360.17260.06150.02980.0599n=150α=0.50.41690.24830.39830.16190.48350.15950.36180.1543β=0.50.42440.26920.38490.16940.36740.12740.36720.1170λ=1-0.02920.03920.02460.03720.05820.03630.01300.0371Table 2
Bias and MSE values forα, β, and λ of the XGAIW distribution.
ParametersMLEsMPSEsLSEsWLSEsBiasMSEBiasMSEBiasMSEBiasMSEn=50α=0.50.92441.32740.88360.93530.72540.64180.85680.7255β=1.50.52431.18350.21940.27320.24640.11650.36390.1715λ=1-0.04300.09860.06990.09740.03560.09180.13580.0934n=100α=0.50.82530.83990.78650.69670.74550.59650.78640.6732β=1.50.38440.45590.28630.12730.28170.11540.27200.1163λ=1-0.01670.04980.05680.04730.08130.04280.02930.0459n=150α=0.50.78630.73680.78550.64670.76550.52650.89200.5808β=1.50.43550.54650.27530.10740.28630.09130.28640.0974λ=1-0.02980.02690.01890.03160.04860.02770.00640.0253Table 3
Bias and MSE values forα, β, and λ of the XGAIW distribution.
ParametersMLEsMPSEsLSEsWLSEsBiasMSEBiasMSEBiasMSEBiasMSEn=50α=0.51.27732.71540.88590.96100.83740.78430.77320.7416β=1.50.47941.98480.28640.44300.32490.36390.26420.1592λ=1.50.22830.21830.13650.17430.06220.12620.01740.1465n=100α=0.51.18462.14670.84730.81720.75280.68170.94150.6958β=1.50.37631.09900.29150.21270.26520.10730.23930.1474λ=1.50.14930.10620.07590.09220.05440.08630.02770.0767n=150α=0.50.96901.21680.79110.62760.86380.58360.26570.4290β=1.50.93151.00920.20150.16780.28300.10190.20540.0816λ=1.50.04260.04320.08170.04200.01830.03970.03730.0383Table 4
Bias and MSE values forα, β, and λ of the XGAIW distribution.
ParametersMLEsMPSEsLSEsWLSEsBiasMSEBiasMSEBiasMSEBiasMSEn=50α=10.59251.22820.28920.25930.20160.10560.14740.1576β=1.50.23361.41580.16680.31760.02780.11630.03690.2530λ=1.5-0.02460.19680.07700.18390.23480.18160.03880.1561n=100α=10.52690.83880.22980.16950.20630.09670.14900.0929β=1.50.06140.75880.06760.16180.13880.10430.04780.0835λ=1.50.13180.11990.05670.10180.00630.08650.03890.0914n=150α=10.32890.43760.34790.12140.14140.06630.17320.0449β=1.50.18530.6479-0.01790.13680.07680.02150.12870.0817λ=1.50.03830.05490.01630.04760.07390.04710.00160.0457Table 5
Bias and MSE values forα, β, and λ of the XGAIW distribution.
ParametersMLEsMPSEsLSEsWLSEsBiasMSEBiasMSEBiasMSEBiasMSEn=50α=1.50.03250.5954-0.29830.2856-0.21210.1190-0.19490.1549β=1.50.04890.8856-0.09410.2955-0.27560.1665-0.25130.2417λ=1.5-0.05870.18900.02430.16480.19220.1346-0.01870.1298n=100α=1.5-0.03560.4279-0.39860.1685-0.29540.1299-0.22890.0956β=1.5-0.17590.5579-0.23990.1899-0.25790.1289-0.12880.1785λ=1.5-0.03790.09830.00850.09790.11990.0950-0.01920.0913n=150α=1.5-0.06650.3356-0.35650.1359-0.25290.0955-0.24550.0908β=1.5-0.07480.4486-0.13640.0956-0.29870.0875-0.21900.0863λ=1.5-0.02210.0557-0.02850.0516-0.03760.04650.05780.0499Figures3–12 present the values of MSEs corresponding with estimate methods MLE, MPE, LSE, and WLSE using Monte Carlo experiments which were carried out based on 10,000 random samples.Figure 3
MSEs usingn=50: α=0.5, β=0.5, and λ=1.Figure 4
MSEs usingn=150: α=0.5, β=0.5, and λ=1.Figure 5
MSEs usingn=50: α=0.5, β=1.5, and λ=1.Figure 6
MSEs usingn=150: α=0.5, β=1.5, and λ=1.Figure 7
MSEs usingn=50: α=0.5, β=1.5, and λ=1.5.Figure 8
MSEs usingn=150: α=0.5, β=1.5, and λ=1.5.Figure 9
MSEs usingn=50: α=1, β=1.5, and λ=1.5.Figure 10
MSEs usingn=150: α=1, β=1.5, and λ=1.5.Figure 11
MSEs usingn=50: α=1.5, β=1.5, and λ=1.5.Figure 12
MSEs usingn=150: α=1.5, β=1.5, and λ=1.5.In Figures3–12, it appears that the WLSE method is the best method.


## 6. An Application for Breast Cancer

In this section, we present an application to breast cancer data set to illustrate the performance and flexibility of the XGAIW distribution and show that XGAIW distribution can be a better model than some recently developed models where the particular data are utilized. This data set is obtained from the “Ministry of Health and Population Egypt” (seehttp://www.statista.com/statistics/1044734/egypt-number-of-cancer-prevalence-cases-general-population-by-type/ (2021)). The data set, given in Table 6, represents 65 patients suffering from breast cancer from one of the ministries of health hospitals in Egypt.Table 6
The lifetime number of days, in increasing order, for 65 patients suffering from breast cancer.
30, 31, 31, 33, 34, 35, 35, 36, 37, 38, 39, 40, 40, 41, 42, 42, 43, 44, 44, 45, 51, 52, 52, 53, 53, 54, 55, 57, 59, 60, 62, 64, 66, 67, 70, 71,73, 74, 75, 77, 78, 84, 85, 87, 90, 93, 100, 101, 103, 105, 108, 125, 130, 134, 150, 150,152, 154, 155, 171, 180, 262, 264, 290, 299.For these breast cancer data set, we compare the XGAIW model with some rival models, namely, the new generalized inverse Weibull distribution (NGIW) by Khan and King, exponentiated generalized inverse Weibull distribution (EGIW) by Elbatal and Muhammed [31], new generalized inverse Rayleigh (NGIR) by Malik and Ahmad [32], modified inverse Weibull (MIW) distribution by Khan and King [33], Kumaraswamy–inverse Weibull distribution (KIW) by Shahbaz M. Q. et al. [34], and inverse Weibull (IW) distribution; see Ibrahim and Almetwally [35].Figures13 and 14 offer the plots of estimated CDF, fitted PDF, Q-Q plot, and P-P plot for the XGAIW distribution for cancer data. Figure 15 indicates that the XGAIW distribution supply better fits to breast cancer data compared to some other distributions.Figure 13
The fitted PDF and estimated CDF of the XGAIW model.Figure 14
The estimated CDF, fitted PDF, P-P plot, and Q-Q plot of the XGAIW distribution for complete breast cancer data.Figure 15
The estimated CDF, fitted PDF, P-P plot, and Q-Q plot of the NGIW, XGAIW, KIW, and NGIR distributions for complete breast cancer data.The selection of models for specific data is one of the basic tasks of the scientific study in choosing a predictive model from a group of candidate models. Several statistical methods are available to determine the fitness of competing distributions, where the most widely used are the Kolmogorov-Smirnov (K-S) statistic and correspondingP value, −2 log-likelihood function (−2ℓ), Akaike information criterion (AIC), the correct Akaike information criterion (CAIC), Bayesian information criterion (BIC), and Hannan-Quinn information criterion (HQIC). However, the better distribution corresponds to the smaller values of AIC, CAIC, BIC, HQIC, and K-S criteria and largest values of P value. These methods are determined according to the following formulas, respectively.The AIC is evaluated as follows:(19)AIC=2k–2ℓ.The CAIC is(20)CAIC=2nkn−k−1–2ℓ.The BIC is given by(21)BIC=klogn–2ℓ.The HQIC is(22)HQIC=2kloglogn–2ℓ,where ℓ is the MLE log-likelihood function value, k is the number of parameters in any distribution, and n is considered as the size of the sample used in calculations.The MLE estimates of the parameters with the corresponding standard errors (SEs) are reported in Table7, while in Table 8, we list the values of AIC, CAIC, BIC, HQIC, and K-S and the P value statistics. We observe that the XGAIW model has the smallest AIC, CAIC, BIC, HQIC, and K-S values and has the largest P value as compared with those values of the other models. So, the XGAIW model seems to be a very competitive model to this data. More information is provided by a visual comparison of the histogram and estimated cumulative of the breast cancer data set as shown in Figures 13–15. It is clear from Figure 15 that the XGAIW distribution provides a better fit for breast cancer data set.Table 7
MLEs and SEs with different models for medical data.
ModelαβληEstimateSEsEstimateSEsEstimateSEsEstimateSEsNGIW187.24830.4951.1360.091219.6418.39718.72922.8363EGIW225.635202.8130.0630.029503.632191.59266.57412.783KIW831.9570.2405.9160.485298.376538.780115.8655.0631NGIR100.249191.9600.6380.336151.42312.817——XGAIW204.139163.9450.4950.06862.458816.395——MIW194.15919.4280.02320.025750.8351.494——IW0.7290.09224.2794.432————Table 8
Goodness-of-fit measures for medical data.
Model−2ℓAICBICCAICHQICK-SP valueNGIW2209.7522217.7522217.0042218.4192211.8190.9950.006EGIW1531.6621549.6621538.9141540.3291533.7920.1050.217NGIR1433.0511439.0511438.4901439.4441434.6010.0560.905XGAIW1219.6071225.6071225.04612261221.1570.0510.934MIW1539.8541545.8541545.2931546.2471541.4040.0660.778KIW1528.9071536.9071536.1591537.5741530.9740.1010.258IW2398.3962402.3962402.0222402.492399.4300.3590.001


## 7. Concluding Remarks

In this paper, we proposed a three-parameter X-Gamma inverse Weibull (XGAIW) distribution, as a new extension of the IW model. The XGAIW density is a linear combination of the IW densities. Some explicit expressions for mathematical quantities of the XGAIW distribution are derived. The new distribution is much more flexible than the IW distribution and could have increasing, decreasing, and unimodal hazard rates. We consider four methods of estimation, namely, the MLEs, MPSEs, LSEs, and WLSEs, to estimate the XGAIW parameters. The performance of these proposed estimation methods is conducted via some simulations. A breast cancer data set application proves that the XGAIW model provides consistently better fits compared to some other rival models.



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*Source: 4693490-2022-06-03.xml*