Journal of Probability and Statistics
Volume 2018 (2018), Article ID 2931326, 12 pages
https://doi.org/10.1155/2018/2931326

Research Article

Extended Odd Fréchet-G Family of Distributions

Suleman Nasiru

Department of Statistics, Faculty of Mathematical Sciences, University for Development Studies, Tamale, Ghana

Correspondence should be addressed to Suleman Nasiru; sulemanstat@gmail.com

Received 8 August 2018; Accepted 10 November 2018; Published 2 December 2018

Academic Editor: Luis A. Gil-Alana

Copyright © 2018 Suleman Nasiru. This is an open access article distributed under the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.

Abstract.

The need to develop generalizations of existing statistical distributions to make them more flexible in modeling real data sets is vital in parametric statistical modeling and inference. Thus, this study develops a new class of distributions called the extended odd Fréchet family of distributions for modifying existing standard distributions. Two special models named the extended odd Fréchet Nadarajah-Haghighi and extended odd Fréchet Weibull distributions are proposed using the developed family. The densities and the hazard rate functions of the two special distributions exhibit different kinds of monotonic and nonmonotonic shapes. The maximum likelihood method is used to develop estimators for the parameters of the new class of distributions. The application of the special distributions is illustrated by means of a real data set. The results revealed that the special distributions developed from the new family can provide reasonable parametric fit to the given data set compared to other existing distributions.

1. Introduction

The fundamental reason for parametric statistical modeling is to identify the most appropriate model that adequately describes a data set obtained from experiment, observational studies, surveys, and so on. Most of these modeling techniques are based on finding the most suitable probability distribution that explains the underlying structure of the given data set. However, there is no single probability distribution that is suitable for different data sets. Thus, this has triggered the need to extend the existing classical distributions or develop new ones. Barrage of methods for defining new families of distributions have been proposed in literature for extending or generalizing the existing classical distributions in recent time. Some of these methods include Weibull-G [1], odd generalized exponential family [2], odd Lindley-G family [3], Topp-Leone odd log-logistic-G family [4], odd Burr-G family [5], odd Fréchet-G family [6], odd gamma-G family [7], transformed-transformer method [8], exponentiated transformed-transformer method [9], exponentiated generalized transformed-transformer method [10], alpha power transformed family [11], alpha logarithmic transformed family [12], Kumaraswamy-G family [13], beta-G family [14], Kumaraswamy transmuted-G family [15], transmuted geometric-G family [16], and beta extended Weibull family [17]. These methods are developed with the motivation of defining new models with different kinds of failure rates (monotonic and nonmonotonic), constructing heavy-tailed distributions for modeling different kinds of data sets, developing distributions with symmetric, right skewed, left skewed, reversed J shape, and consistently providing a reasonable parametric fit to given data sets.

Recently, [6] developed the odd Fréchet family of distributions and defined its cumulative distribution function (CDF) as

where is the baseline CDF and is a vector of associated parameters. Using the transformed-transformer method proposed by [8], an extension of the odd Fréchet family of distributions called the extended odd Fréchet-G (EOF-G) family of distributions is developed by integrating the Fréchet probability density function (PDF). Hence, the CDF of the EOF-G family is defined as

where and are extra shape parameters. The corresponding PDF of the new family is obtained by differentiating equation (2) and is given by

The associated hazard rate function of the EOF-G family is defined as

Hereafter, a random variable following the EOF-G distribution is denoted by and for the purpose of simplicity, can be written as . The CDF of the EOF-G family of distributions is tractable which makes it easy to generate random numbers provided that the CDF of the baseline distribution is also tractable. The quantile of the EOF-G family is given by

where is the baseline quantile function. When , the EOF-G family of distributions reduces to the odd Fréchet family of distributions. Adopting the interpretation of the CDF of the odd Weibull family as given in [18], the physical interpretation of the CDF of the EOF-G family is given as follows: Suppose is a lifetime random variable with continuous CDF, . The odds ratio that an individual (component) having the lifetime will die (fail) at time is . Given that the variability of these odds of death is denoted by the random variable and that it follows the Fréchet distribution, then

which is given in (2). The rest of the paper is organized as follows: In Section 2, special distributions of the EOF-G family are discussed. In Section 3, the mixture representation of the PDF and CDF of the EOF-G family is given. The statistical properties of the new family are derived in Section 4. In Section 5, the estimators for the parameters of the family are developed using the technique of maximum likelihood estimation. Monte Carlo simulations are performed in Section 6 to assess the performance of the estimators. In Section 7, the application of the special distributions is demonstrated using real data set. Finally, the concluding remarks of the study are given in Section 8.

2. Special Distributions of the EOF-G Family

In this section, two special distributions of the EOF-G family are discussed.

2.1. EOF-Nadarajah-Haghighi (EOFNH) Distribution

Suppose the baseline CDF is that of the Nadarajah-Haghighi distribution; that is, with corresponding PDF and positive parameters . The PDF of the EOFNH distribution is given by

where are shape parameters, is a scale parameter, and . Figure 1 shows the plots of the PDF of the EOFNH distribution for some selected parameter values. The density function exhibits different kinds of shapes.

Figure 1: Plots of the EOFNH distribution density function.

The corresponding hazard rate function is given by

The plots of the hazard rate function of the EOFNH distribution for some selected parameter values are shown in Figure 2. The hazard rate function can assume decreasing, bathtub, upside down bathtub, and other nonmonotonic failure rate forms.

Figure 2: Plots of the EOFNH distribution hazard rate function.

The quantile function of the EOFNH distribution is given by

Equation (9) can be used to generate random numbers from the EOFNH distribution. The first quartile, median, and upper quartile of the distribution are obtained by substituting , and , respectively, into (9).

2.2. EOF-Weibull (EOFW) Distribution

Consider the Weibull distribution with shape parameter and scale parameter , where the CDF and PDF for are given by and . Substituting the PDF and CDF of the Weibull distribution in (3), the PDF of the EOFW distribution is defined as

where are shape parameters, is scale parameter, and . Figure 3 displays some of the possible shapes of the density function of the EOFW distribution. The density exhibits unimodal and reversed J-shape among others.

Figure 3: Plots of the EOFW distribution density function.

The hazard rate function of the EOFW distribution is given by

The hazard rate function can assume decreasing, bathtub, and upside down bathtub forms for some selected parameter values as shown in Figure 4.

Figure 4: Plots of the EOFW distribution hazard rate function.

The quantile function of the EOFW distribution is defined as

The generation of random numbers from the EOFW distribution can easily be done using (12).

3. Mixture Representation

In this section, the mixture representation of the PDF and CDF of the EOF-G family of distributions is discussed. The mixture representation is useful when deriving the statistical properties of this new family of distributions. Using the Taylor series expansion, the PDF can be written as

Equation (13) can be written as

Applying the generalized binomial series expansion yields

Now using the binomial series expansion, , thrice yields

where

Alternatively (16) can be written in terms of the exponentiated-G (exp-G) density function as

where and is the exp-G density function with power parameter . By integrating (18), the mixture representation of the CDF is given by

where is the CDF of the exp-G family with power parameter .

4. Statistical Properties

In this section, the moments, incomplete moments, generating function, entropies, and order statistics of the EOF-G family are derived.

4.1. Moments

The noncentral moment of a random variable is given by . Hence, using this definition the noncentral moment of the EOF-G random variable is given by

where is the probability weighted moment of the baseline distribution. The noncentral moment can also be expressed in terms of the quantile of the baseline distribution. Letting , the noncentral moment in terms of the quantile is given by

where is the quantile function of the baseline distribution.

4.2. Incomplete Moments

The incomplete moment of a random variable is defined as . Thus, the incomplete moment of the EOF-G random variable is given by

In terms of the quantile function of the baseline distribution, the incomplete moment is given by

Utilize the power series expansion of the quantile of the baseline; that is,

where are suitably chosen real numbers that depend on the parameters of the distribution. Furthermore, for positive integer ,

where and . For more details on quantile power series expansion, see [19]. Hence,

The incomplete moments are used in the computation of other useful statistical measures such as the mean deviations about the mean and about the median . The mean deviation about the mean and about the median can further be expressed as

where is the mean obtained by putting into (20), is the median obtained by substituting into (5), and is the first incomplete moment which can be obtained from (23) by substituting .

4.3. Generating Function

In this subsection, two formulae for the computation of the moment generating function are given. Using the Taylor series expansion, . Thus, the moment generating function is given by

Alternatively, the moment generating function can be expressed in terms of the quantile function of the baseline distribution as

4.4. Entropy Measures

Entropies are measures of uncertainty or variation of a random variable. In this subsection, the Rényi, Shannon, and entropies are studied. The Rényi entropy [20] of a random variable with PDF is defined as

Using similar concepts for expanding the PDF,

where

Hence,

The Shannon entropy [21] of a random variable , say . The Shannon entropy is a special case of the Rényi entropy when . The entropy is given by

Thus, the entropy is

4.5. Order Statistics

Let represent a random sample from EOF-G family and be the order statistics. Then the PDF, , of the order statistic is

Substituting the PDF and the CDF of the EOF-G random variable into the last equation yields

after some algebraic manipulation, where

The PDF of the order statistic can be expressed in terms of the exp-G density function as

where and is the exp-G density function with power parameter .

5. Parameter Estimation

In this section, the maximum likelihood technique is employed to develop estimators for estimating the parameters of the EOF-G family of distributions. Suppose are possible outcomes of a random sample obtained from and is a parameter vector; then the total log-likelihood function is given by

By finding the partial derivatives of (40), the components of the score vector are

where and . In order to obtain the estimators for the parameters, we set (41), (42), and (43) to zero and solve the system numerically using methods such as the quasi-Newton algorithms since the equations do not have closed form. To obtain interval estimates of the parameters, a observed information matrix can be estimated as (for ), whose elements are evaluated numerically. To compute the approximate confidence intervals of the parameters, the multivariate normal distribution . Here, is the observed information evaluated at . To investigate whether the EOF-G distributions are superior to the odd Fréchet family of distributions for given data sets, the likelihood ratio (LR) test can be performed using the following hypotheses: versus is false. The LR test statistic is given by , where is the vector of unrestricted estimates under and is the vector of restricted maximum likelihood estimates under . The LR test statistic is asymptotically distributed as Chi-square random variable with degrees of freedom equal to the difference between the numbers of parameters of the two models. As a decision rule, the null hypothesis is rejected when the LR test statistic exceeds the upper quantile of the Chi-square distribution.

6. Simulation Study

In this section, Monte Carlo simulations are performed to assess the accuracy and consistency of the maximum likelihood estimators. For the purpose of illustration, the simulations are performed using the estimators of the parameters of the EOFNH distribution. The quantile function given in (9) is used to generate random observations from the EOFNH distribution. The simulations are repeated times each with sample size and parameter values , , and . Table 1 presents the average bias (AB), the root mean square error (RMSE), and coverage probability (CP) of the confidence intervals for the estimators of the parameters. The results indicated that the ABs and RMSEs decrease as the sample size increases. These results clearly show the accuracy and the consistency of the maximum likelihood estimators. Also, the CPs are quite close to the nominal value. Thus, the maximum likelihood technique works very well to estimate the parameters of the EOFNH distribution.

Table 1: Monte Carlo simulation results: AB and RMSE and CP.

I
II
III

Parameter

AB
RMSE
CP
AB
RMSE
CP
AB
RMSE
CP

25
0.5406
1.9394
0.9780
24.9701
133.9291
0.9160
3.1057
17.0755
0.8780

75
0.1710
0.5134
0.9470
12.5503
76.6534
0.9030
1.1174
3.9980
0.8850

150
0.0919
0.3459
0.9120
5.6552
41.2149
0.9200
0.4664
1.3878
0.9020

300
0.0242
0.2526
0.8670
2.1667
5.1107
0.9540
0.2038
0.6941
0.9280

600
-0.0043
0.2076
0.8300
0.9715
2.8387
0.9640
0.1071
0.4109
0.9430

800
-0.0010
0.1794
0.8670
0.7123
2.3503
0.9560
0.0623
0.3374
0.9430

25
0.0040
0.2147
0.9620
0.4450
1.3048
0.9810
0.0212
0.1894
0.9920

75
0.0488
0.3523
0.9630
0.2138
0.5569
0.9880
0.0163
0.1195
0.9830

150
0.0740
0.4896
0.9620
0.1105
0.3330
0.9890
0.0117
0.0705
0.9680

300
0.0890
0.4095
0.975
0.0633
0.2147
0.9720
0.0068
0.0438
0.9620

600
0.066
0.2745
0.9670
0.0324
0.1275
0.9630
0.0032
0.0296
0.9520

800
0.0357
0.1378
0.9730
0.0264
0.1105
0.9620
0.0021
0.0255
0.9510

25
12.5655
249.9064
0.9340
3.7073
32.1823
0.8930
4.9031
47.5403
0.8170

75
0.6886
2.7878
0.8530
1.2894
15.0985
0.8850
1.4279
12.6625
0.8460

150
0.3001
0.9320
0.8280
0.1493
2.7383
0.9200
0.2900
1.9911
0.8740

300
0.1265
0.5992
0.8020
0.0298
0.1599
0.9490
0.0726
0.2735
0.8950

600
0.0400
0.4286
0.7900
0.0075
0.0931
0.9800
0.0375
0.1450
0.9320

800
0.0351
0.3629
0.8400
0.0053
0.0856
0.9670
0.0227
0.1175
0.9300

25
0.0856
0.3163
0.9999
0.4125
1.7492
0.8970
0.1846
0.5637
0.9810

75
0.0616
0.2515
0.9800
0.1192
0.8350
0.8370
0.0725
0.3927
0.9290

150
0.0599
0.2400
0.9500
0.1242
0.7001
0.8280
0.0599
0.3320
0.9310

300
0.0790
0.2422
0.9200
0.0602
0.4882
0.8550
0.0435
0.2675
0.9260

600
0.0824
0.2313
0.8840
0.0506
0.3537
0.8940
0.1230
0.1618
0.9400

800
0.0601
0.1957
0.9040
0.0396
0.3043
0.9130
0.0179
0.1502
0.9410

7. Application

In this section, the application of the EOFNH and EOFW distributions is illustrated using a real data set. The data consists of the Fatigue time of 101 6061-T6 aluminum coupons cut parallel to the direction of rolling and oscillated at 18 cycles per second. The data set given in Table 2 can be found in Birnbaum and Saunders [22]. The performance of the EOFNH and EOFW distributions is compared with that of the odd Fréchet Nadarajah-Haghighi (OFNH) and odd Fréchet Weibull (OFW) distributions using the Akaike information criterion (AIC) [23, 24] and Bayesian information criterion (BIC) [25]. The maximum likelihood estimates of the parameters of the fitted distributions are computed by maximizing the log-likelihood function via the subroutine mle2 uisng the bbmle package in the R software [26].

Table 2: Fatigue time of 101 6061-T6 aluminum coupons.

70
90
96
97
99
100
103
104
104
105
107
108
108
108
109

109
112
112
113
114
114
114
116
119
120
120
120
121
121
123

124
124
124
124
124
128
128
129
129
130
130
130
131
131
131

131
131
132
132
132
133
134
134
134
134
134
136
136
137
138

138
138
139
139
141
141
142
142
142
142
142
142
144
144
145

146
148
148
149
151
151
152
155
156
157
157
157
157
158
159

162
163
163
164
166
166
168
170
174
196
212

The PDFs of the OFNH and OFW distributions are, respectively, given by

and

Table 3 displays the maximum likelihood estimates of the parameters of the EOFNH, EOFW, OFNH, and OFW distributions with their corresponding standard errors in bracket and the model selection criteria. The results revealed that the EOFNH distribution provided the best fit for the data since it has the least values of AIC and the BIC. The EOFW distribution also performed better than the OFNH and OFW distributions. The OFNH distribution is a submodel of the EOFNH distribution with . Hence, testing versus using the LR test gave a test statistic of 6.4703 with corresponding value of 0.01097. This implies that there is enough evidence to reject at the significance level and conclude that the EOFNH distribution provides better fit to the data than the OFNH distribution. Similarly, the LR test was performed to compare the performances of the EOFW distribution and the OFW distribution. The analysis gave a test statistic of 5.1065 with a corresponding value of 0.0238. This implies that the EOFW distribution performs better than the OFW distribution at the significance level.

Table 3: Maximum likelihood estimates and goodness-of-fit statistics.

Model
Parameter estimates

AIC
BIC

EOFNH

-470.3600
948.7255
959.1860

OFNH

-473.6000
953.1958
961.0412

EOFW

-471.2600
950.5259
960.9864

OFW

-473.8200
953.6325
961.4778

Figure 5 displays the histogram of the data with the fitted densities and the empirical CDF with the fitted CDFs.

Figure 5: Plots of histogram of data and fitted densities; and empirical CDF and fitted CDF.

The P-P plots of the fitted distributions are displayed in Figure 6.

Figure 6: P-P plots of fitted distributions.

8. Conclusion

The development of new statistical distribution plays a critical role in parametric statistical inference. Because of this, researchers in the field of distribution theory attempt to develop generators for generalizing the existing distributions. In line with this, the study developed and studied a new class of distributions called the EOF-G family. The statistical properties including the moments, incomplete moments, generating function, entropies, and order statistics are derived. The maximum likelihood method is used to develop estimators for the parameters of the new family. The application of the special distributions developed using the EOF-G family is demonstrated using a real data set and the result compared with other existing distributions. From the application, it is evident that the special models developed from the EOF-G family can provide reasonable parametric fit to a given data set. Hence, it is hoped that the new class of distributions will attract wider applications in different fields of study.

Data Availability

The data used to support the findings of this study are available from the corresponding author upon request.

Conflicts of Interest

The author declares that there are no conflicts of interest regarding the publication of this article.

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