Computer Systems Science & Engineering DOI:10.32604/csse.2021.017362 | ![]() |
Article |
Inverse Length Biased Maxwell Distribution: Statistical Inference with an Application
1Department of Mathematics, Faculty of Science, Al al-Bayt University, Mafraq, Jordan
2Department of Mathematics, College of Science and Human Studies at Hotat Sudair, Majmaah University, Majmaah 11952, Saudi Arabia
*Corresponding Author: Ayed R. A. Alanzi. Email: a.alanzi@mu.edu.sa
Received: 28 January 2021; Accepted: 14 March 2021
Abstract: In this paper, we suggested and studied the inverse length biased Maxell distribution (ILBMD) as a new continuous distribution of one parameter. The ILBMD is obtained by considering the inverse transformation technique of the Maxwell length biased distribution. Statistical characteristics of the ILBMD such as the moments, moment generating function, mode, quantile function, the coefficient of variation, coefficient of skewness, Moors and Bowley measures of kurtosis and skewness , stochastic ordering, stress-strength reliability, and mean deviations are obtained. In addition, the Bonferroni and Lorenz curves, Gini index, the reliability function, the hazard rate function, the reverse hazard rate function, the odds function, and the distributions of order statistics for the ILBMD, are presented. The ILBMD parameter is estimated using the maximum likelihood method, the method of moments, the maximum product of spacing technique, the ordinary and weight least square procedures, and the Cramer-Von-Mises methods. The Fishers information, as well as the Rényi and q-entropies, are derived. To investigate the usefulness of the proposed lifetime distribution and to illustrate the purpose of the study, a real dataset of the relief times of 20 patients receiving an analgesic is used.
Keywords: Maxell distribution; inverse length biased Maxwell distribution; Fisher’s information; methods of estimation; goodness of fit tests
A random variable W follows a Maxwell distribution with scale parameter α , if its probability density function (pdf) and cumulative distribution function (cdf), respectively, are given by
fMD(w;α)=√2πw2α3e−w22α2,0<w<∞,α>0, (1)
FMD(w;α)=Erf(wα√2)wα√2πe−w22α2, (2)
where Erf(z)=2√πz∫0e−t2dt . In the literature of the probability distributions, uni-modal and skewed to the right characteristics are very important to the distribution of interest. One of these distributions is the Maxwell distribution, which is a well-known lifetime distribution in physics and statistical mechanics. Reference Iriarte et al. [1] suggested a gamma-Maxwell distribution. The tail behavior of the generalized Maxwell distribution is considered by Huang et al. [2]. Recently, Saghir et al. [3] suggested a length-biased Maxwell distribution (LBMD) as a modification of the base Maxwell distribution based on the weighted distribution suggested by Rao et al. [4], to obtain the probability density function given by:
fLBMD(w;α)=w32α4e−w22α2,0<w<∞,α>0, (3)
and a cumulative distribution function defined as
FLBMD(w;α)=1−(w22α2+1)e−w22α2,0<w<∞,α>0. (4)
The mode and median of the LBMD are wM=α√3 and E(W)=3α4√2π , respectively. For more information about the LBMD see [3]. Due to the large number of data in these times, a large number of distributions are suggested based several philosophies, assuming that the suggested distributions are more flexible in modeling data. For example, [5] introduced Marshall–Olkin length-biased Maxwell distribution. Reference Singh et al. [6] suggested length-biased weighted Maxwell distribution and [7] considered estimation of the inverse Maxwell distribution parameter. Reference Garaibah et al. [8] suggested size-biased Ishita distribution and [9] introduced transmuted Ishita distribution. The Marshall-Olkin length-biased exponential distribution is proposed by Shraa et al. [10]. A new mixture continuous Darna distribution is suggested by Al-Omari et al. [11,12] proposed length-biased Suja distribution. Reference Sharma et al. [13] studied the power size biased two-parameter Akash distribution with some statistical properties and real data applications. Reference Al-Omar et al. [14] proposed length and area biased Maxwell distributions. Reference Gharaibeh [15] suggested Top-Leone Mukherjee-Islam distribution and [16] proposed transmuted Aradhana distribution.
The rest of this paper is organized as follows: In Section 2, we present the derivation of the suggested distribution. Section 3 deals with the main statistical properties of the ILBMD. Different methods of estimation for the distribution parameter are given in Section 4. In Section 5, a simulation study is conducted to investigate the distribution. An application of real data is presented in Section 6 and the paper is concluded in Section 7.
2 Derivation of the Suggested Model
If a random variable W has a LBMD with pdf given in (3), then the random variable X=1W is said to follow the inverse LBMD. The pdf and cdf of the inverse length-biased Maxwell distribution (ILBMD), respectively are given by
fILBMD(x;α)=12α4x5e−12α2x2,0<x<∞,α>0, (5)
and
FILBMD(x;α)=(1+12α2x2)e−12α2x2,0<x<∞,α>0. (6)
Plots of the pdf and cdf of the ILBMD are presented in Fig. 1 for various distribution parameter. Fig. 1, revealed that the pdf of the suggested distribution is skewed to the right and be more flatting as α values are increasing. Also, the pdf of the ILBMD can exhibit various behavior depending on the values of the parameter.
Figure 1: The ILBMD pdf and cdf plots for α=0.1,0.2,0.3,0.4,0.5
In this section, the main properties if the proposed model are presented.
The reliability is a well-known in engineering where it gives the probability for surviving at least time t of a product operate, while the hazard function shows the nature of failure rate related to the product. Generally, the reliability and hazard functions are fundamental to study the characteristics of the time to event data. Figs. 2 and 3 are the plots of the hazard, reliability reversed hazard, and the odds functions of the ILBMD for α=0.1,0.2,0.3,0.4,0.5 .
• Hazard rate function: The hazard rate (HR) function is a very important property in characterizing any lifetime distribution. The HR of the ILBMD is given by
HILBMD(x;α)=fILBMD(x;α)1−FILBMD(x;α)=12α4x5e−12α2x21−(1+12α2x2)e−12α2x2. (7)
Figure 2: The hazard (A) and reliability (B) functions of the ILBMD plots for α=0.1,0.2,0.3,0.4,0.5
Figure 3: The reverse hazard (A) and odds (B) functions of the ILBMD plots for α=0.1,0.2,0.3,0.4,0.5
To determine the shape of the HR function we followed the technique of [17] which is defined as Φ(x;α)=−f/(x;α)f(x;α) which only depends on the pdf of the distribution. He proved that if Φ/(x)>0 for all x∈(0,x0) , while Φ/(x0)=0 , and Φ/(x)<0 for all x∈(x0,∞) , the distribution has upside down bathtub hazard rate (UBT). For the ILBMD we have Φ(x;α)=5x−1x3α2 and Φ/(x;α)=3α2x4−5x2 . Now, it is found that Φ(√3/5α;α)=0 , that is x0=√3/5α , and hence for the ILBMD we have that Φ(x;α) is increasing on the interval (0,√3/5α) and it is decreasing on the interval (√3/5α,∞) as illustrated in Fig. 2A. Therefore, the proposed ILBMD is useful in reliability data and medical fields due its skewness to the right with UBT shape of hazard rate function.
• Reliability function: The reliability function of the ILBMD distribution is
RILBMD(x;α)=1−FILBMD(x;α)=1−(1+12α2x2)e−12α2x2 (8)
Fig. 2B shows that the reliability plots of the ILBMD intersect at the point f(x)=1 for x=0 , while as x goes to infinity, the reliability function decreases and goes to zero.
• Reversed hazard function: The reversed hazard function of the ILBMD is defined as
RHILBMD(x;α)=fILBMD(x;α)FILBMD(x;α)=12α2x2+1 (9)
• Odds function: The odds function of the ILBMD is given by
OILBMD(x;α)=FILBMD(x;α)1−FILBMD(x;α)=2α2x2+12α2x2e12α2x2−2α2x2−1. (10)
Based on Fig. 3 it can be noted that the reversed hazard decreases with negative J-shaped distribution, while the odds function increases taking the J-shaped with more flatting for small amounts of the parameter α .
In this section, the mode of the ILBMD is derived. Since the pdf fILBMD(x;α) of the model and its logarithm are maximized at the same point, then for simple calculation, take the derivative of the logarithm of the function fILBMD(x;α) as
Υ=lnfILBMD(x;α)=−ln(2α4x5)−12α21x2.The derivative of Υ with respect to x yields ∂Υ∂x=−5x+12α22x3. Equating the preceding derivative to 0 leads to −5x+12α22x3=0 and xMode=±1√5α. But since α>0 , then the mode of the ILBMD is xMode=1√5α. It is clear that the distribution is a unimodal and the mode decreases with increases values of α.
3.3 Moments and Quantile Function
In this section, we derived the various moments of the suggested ILBMD as
• Let X∼fILBMD(x;α) , then the rth moment of X is
E(XrILBMD)=Γ(2−r2)2r2αr,α>0,r=1,2,3,... (11)
• If X∼fILBMD(x;α) , then the moment generating function of X is
MILBMD(t)=t4log[e]4MeijerG[{{},{}},{{−2,−32,0},{}},t2log[e]28α2]64√πα4,α>0, (12)
where MeijerG((a1…anan+1…ap),(b1…bmbm+1…bq),z) is the Meijer G function Gmnpq(z|a1…apb1…bq) .
From Eq. (11), the first and second moments of the ILBMD, respectively, are given as
E(X1ILBMD)=12α√π2 and E(X2ILBMD)=12α2 .
• The variance of the ILBMD is
Var(XILBMD)=E(X2ILBMD)−(E(X1ILBMD))2=12α2−(12α√π2)2=4−π8α2. (13)
• The degree of long-tail is measured by skewness (Sk) and for the ILBMD it is given by
SkILBMD=2(π−2)√π(−1π−4)3/2=5.08834. (14)
• The coefficient of variation of the ILBMD is
CvILBMD=2√2π√12α2−π8α2α4(α2)3/2=√4π−1=0.522723, (15)
which is a very small value.
• Let X∼fILBMD(x;α) , then the rth order inverse moment about the origin of X is
E(1XrILBMD)=2r2αrΓ(2+r2),r=1,2,3,... (16)
Based on Eq. (6), the harmonic mean of the ILBMD distribution can be obtained for r=1 as given by
E(1XILBMD)=32√π2α. (17)
If Q(k) is the quantile function of order k of the ILBM random variable, then it can be the solution of the equation
lnk+12α2Q2(k)=ln(1+12α2Q2(k)). (18)
The Moors and Bowley measures of kurtosis and skewness, respectively, are given by
Mk=Q(78)−Q(58)+Q(38)−Q(18)Q(68)−Q(28)andBsk=Q(34)−2Q(12)+Q(14)Q(34)−Q(14). (19)
Theorem: Let X∼fILBMD(x;α) , then the Fisher’s information of α is FIILBMD(α)=8α2.
Proof: To find the Fisher’s information of the ILBMD, we have
lnfILBMD(x;α)=−5log[x]+log[12α4]−12α2x2.The first derivative of this function with respect to α yields
∂lnfILBMD(x;α)∂α=2e12x2α2x5(e−12x2α22x7α7−2e−12x2α2x5α5)α4.Again differentiate the last equation with respect to α to get
∂2lnfILBMD(x;α)∂α2=8α3x5e12α2x2(e−12α2x22α7x7−2e−12α2x2α5x5)−2αx3e12α2x2(e−12α2x22α7x7−2e−12α2x2α5x5)+2e12x2α2x5(e−12x2α22x9α10−11e−12x2α22x7α8+10e−12x2α2x5α6)α4.Now, take the expectation of ∂2lnfILBMD(x;α)∂α2 as
−E(∂2lnfILBMD(x;α)∂α2)=−∞∫0∂2lnfILBMD(x;α)∂α212α4x5e−12α2x2dx=8α2.This information is very helpful in determining the variance of estimator or lower bound of an estimator.
Let X(1:n),X(2:n),...,X(n:n) be the order statistics of the random sample X1,X2,...,Xn selected from a pdf and cdf fILBMD(x;α) and FILBMD(x;α) , respectively. The pdf of the ith order statistics say X(i:n) , is
f(i:n)(x)=n!(i−1)!(n−i)![F(x)]i−1[1−F(x)]n−if(x)=n!(i−1)!(n−i)!n−i∑k=0(−1)k(n−ik)12α4x5(1+12α2x2)k+i−1(e−12α2x2)k+i, (20)
and the corresponding cdf is defined as
F(i:n)(x)=n∑j=t(nj)F(x)]j[1−F(x)]n−j=n∑j=tn−i∑k=0(−1)k(nj)(n−ik)[(1+12α2x2)e−12α2x2]j+k. (21)
The stochastic ordering can be considered to compare the behavior of two random variables. Let X and Y be two random variables, then X is said to be smaller than in
1) Mean residual life order
2) Likelihood ratio order
3) Hazard rate order
4) Stochastic order
Based on these relations, we have
Theorem 2: Let
Proof: Based on the concept of the likelihood ratio order, we have
where its logarithm is
The first derivative of this equation with respect to x is
Now, if
3.7 Mean and Median Deviations
This section, introduced the mean and median deviations of the ILBMD,
where
Theorem: Let
where Erfc is the complementary function of the error function erfc, and
Since the median of the ILBMD is
The qth quantile xq of the ILBMD can be found by solving the equation
3.8 Gini Index and Some Curves
Let X be a non-negative random variable with a continuous twice differentiable cumulative distribution function
The Gini index for the ILBMD is given by
It is clear that the Gini index value is small and it is about 0.24. The Bonferroni curve for the ILBMD is defined as
The Lorenz curve for the ILBMD is defined as
3.9 Stress-Strength Reliability
Let X and Y be independent random variables observed from the pdf
Theorem: Let the random variables X and Y be independent selected from the ILBMD. The stress-strength reliability is given by
The Rényi entropy is defined as
• Let
• The q-entropy, say
4 Different Methods of Estimation
In this section, we discuss different estimation procedures for estimating the unknown suggested model parameter.
Let
The log likelihood function is given by
The derivative of
The mean of the ILBMD random variable is
4.3 Cramèr–von-Mises Estimation
Let
For the proposed ILBMD, the Cv estimator,
with respect to
4.4 Ordinary and Weighted Least Squares Methods
Let
For the ILBMD, the LS estimator,
with respect to
with respect to
with respect to
4.5 Method of Maximum Product of Spacing
The maximum product of spacing (MPS) method as suggested by Cheng et al. [20,21] is a powerful alternative to the MLE method for estimating the parameters of continuous distributions. Reference Shanker et al. [22] showed that the MPS method possess similar properties as the MLE method.
Let uniform spacing’s of a random sample of size n uniform spacing’s is given as be
where
Or, equivalently, by maximizing the function
Now, the MPS estimate of the ILBMD parameter
In this section, we compared the various suggested estimators of the model parameters. We selected the values of the parameters
Table 1: Estimates and MSEs with MLE, CV, and MOM methods for the ILBMD with
Table 2: Estimates and MSEs with LS, WLS, and MPS methods for the ILBMD with
The bias of the suggested estimators is very small and goes to zero for all cases considered in this study. Also, as the samples sizes increase the MSE of all proposed estimators decreases.
In this section, we use lifetime data set to compare the fit of the suggested ILBMD distribution with four competitors distributions: Rani, length-biased Maxwell distribution, Rama, and exponential defined as
1) Rani distribution (Rn) suggested by Shanker et al. [23] with pdf given by
2) Length-biased Maxwell distribution (LBM),
3) Rama distribution (Rm) suggested by Gross et al. [24] with pdf given by
4) Exponential distribution (Exp),
The data set given in this section represents the relief times of 20 patients receiving an analgesic. This data set was taken from [25] and it is: 1.1, 1.4, 1.3, 1.7, 1.9, 1.8, 1.6, 2.2, 1.7, 2.7, 4.1, 1.8 ,1.5, 1.2, 1.4, 3.0, 1.7, 2.3, 1.6, 2.0.
In order to compare the two models, we consider the Akaike Information Criterion (AIC), Consistent Akaike Information Criterion (CAIC), Hannan-Quinn Information Criterion (HQIC), and Bayesian Information Criterion (BIC). The generic formulas for finding AIC, CAIC, HQIC, and BIC are respectively, given as
Table 3: Model comparison using AIC, CAIC, BIC, HQIC, -2logL, and the KS test criterion for the 20 patients data
Hence, we can deduce that the inverse length biased Maxwell distribution leads to a better fit than the Rama, Rani, length biased Maxwell and exponential distribution. The Kolmogorov Smirnov p-value suggests that inverse length biased Maxwell distribution fits statistically better than other distributions considered in this example to the 20 patients data set. Plots of the fitted densities and the histogram are given in Fig. 4.
Figure 4: The fitted pdfs of the Rama, Rani, LBM, Exp and ILBM models
In this article, we introduced and studied the ILBMD. Some statistical properties of the ILBMD are derived and discussed. The reliability and hazard functions of the distribution are analyzed. Also, the distribution of order statistics, mode, harmonic mean, Fisher's information, the stochastic ordering and the mean deviations about the mean and median are presented. The distribution parameter is estimated using different estimation methods includes the maximum likelihood estimation, method of moments, maximum product of spacing, ordinary and weight least square procedures, and the Cramer-Von-Mises methods. The q and Rényi entropies are derived as well as the stress strength reliability is obtained. A real data sets is considered to support the paper objectives. It is revealed that the ILBMD is more power than its competitors used in this study. As a future works the distribution parameter can be estimated based on ranked set sampling method, see [26–32].
Acknowledgement: The authors are grateful to the Editor and anonymous reviewers for their valuable comments and suggestions.
Funding Statement: A.R.A. Alanzi would like to thank the Deanship of Scientific Research at Majmaah University for financial support and encouragement.
Conflicts of Interest: The authors declare that they have no conflicts of interest.
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