ISSN(Print): 2328-7306
ISSN(Online): 2328-7292

Article Versions

Export Article

Cite this article

- Normal Style
- MLA Style
- APA Style
- Chicago Style

Research Article

Open Access Peer-reviewed

Yasser M. Amer^{ }, Dina H. Abdel Hady, Rania M. Shalabi

Received December 10, 2020; Revised January 11, 2021; Accepted January 20, 2021

In this paper two basic random variables constructed from Quasi Lindley distribution have been introduced. One of these variables is defined as the sum of two independent random variables following the Quasi-Lindley distribution with the same parameter (2SQLindley). The second one is defined as the difference of two independent random variables following the Quasi-Lindley distribution with also the same parameter (2DQLindley). For both cases, we provided some statistical properties such as moments, incomplete moments and characteristic function. The parameters are estimated by maximum likelihood method. From simulation studies, the performance of the maximum likelihood estimators has been assessed. The usefulness of the corresponding models is proved using goodness-of-fit tests based on different real datasets. The new models provide consistently better fit than some classical models used in this research.

The analysis and modeling of lifetime data are very important in applied sciences such as engineering, public health, actuarial science, biomedical studies, demography, industrial reliability and other applied sciences. For this reason, it became really urgent to find statistical distributions to handle these real models data. The one of these distributions, is Lindley distribution which was introduced by ^{ 1} to analyze failure time data especially in applications modeling stress-strength reliability. The importance of the Lindley distribution comes from its power to model failure time data with increasing, decreasing, unimodal and bathtub-shaped hazard rates. Lindley distribution can be written as a mix of exponential and gamma distributions. The properties and inferential procedure for the Lindley distribution were studied by ^{ 2}. It is shown that the Lindley distribution is better than the exponential distribution when the hazard rate is unimodal or bathtub shaped.

Generalizations and transformations of existing distribution attract the statistical research to develop new models to prove useful in exploring skewness and tail properties, and also to improve the goodness-of-fit of the extended family. Lindley distribution has been generalized, extended, modified and mixed with other discrete distributions by many authors in recent years. ^{ 3} referred to the three Parameters-Lindley distribution, ^{ 4} introduced generalized Poisson-Lindley distribution, generalized Lindley distribution has been proposed by ^{ 5}. Further, more investigations applied to Lindley distribution to improve its performance and have been introduced by some interested researchers. For example; Marshall-Olkin Lindley distribution was introduced by ^{ 6}, power Lindley distribution was presented by ^{ 7}, two-parameter Lindley distribution by ^{ 8}, Quasi Lindley distribution by ^{ 9}, transmuted Lindley distribution by ^{ 10}, transmuted Lindley-geometric distribution and beta-Lindley distribution by ^{ 11}. A retrospective study on Lindley distribution and its generalizations have been studied extensively by ^{ 12} and discrete Harris extended Lindley distribution by ^{ 13}. A latest version of the Lindley distribution, called modified Lindley distribution, is introduced by ^{ 14}.

Recently, ^{ 15} have been introduced Generalization of the Lindley distribution based on the formation of a distribution of the sum of two iid variables that have a Lindley distribution with the same parameters and are independent. They also presented a distribution of the difference between the same two variables, where the results applied on real data sets provided consistently better fit than some classical distributions.

In this paper we will present a distribution of the sum of two iid variables that have a Quasi-Lindley distribution with the same parameters and are independent, where the Quasi - Lindley distribution is considered one of the generalizations of the Lindley distribution. Quasi - Lindley distribution, Lindley distribution and the exponential distribution in order to demonstrate the quality of reconciliation on the real data set. Also, the distribution of the difference between the two variables will be compared with both Laplace distribution and the distribution of the sum of two independent variables each of which has the same Laplace distribution with the same parameters to demonstrate the good of fit on the real data set.

The cumulative distribution function (cdf) and the probability density function (pdf) of quasi-Lindley distribution (QLD) of ^{ 8} are given by;

(1) |

(2) |

This section is focused on definitions and some properties of the sum of two independent random variables following the Quasi Lindley distribution (2SQLindely).

We consider the pdf given by

(3) |

The feature of this distribution is the following: let and be two independent random variables following the Quasi Lindley distribution (QL) with parameters and Then, the random variable has the pdf given by (3). This result is a particular case of ^{ 16}. The proof is as follow; Since and are independent, the pdf of is given by the convolution product

This distribution is considered entirely new as it has not been previously deduced and is considered a generalized distribution for the distribution of the sum of two independent variables for which the Lindley distribution provided by ^{ 15}. Whereas, through this research and in what part if is placed, we obtain the same results as that of ^{ 15}.

First of all, after some algebraic manipulations, the cdf of the 2SQLindely distribution is given by

(4) |

Moreover, the survival function is given as follows

(5) |

The hazard rate function, hrf, is given by

(6) |

Also, the corresponding cumulative hazard rate function, hrf, is given by

(7) |

he corresponding quantile function (qf), say can be obtained by solving the following equation: It cannot be presented analytically but can be determined numerically for a given and

Figure 1, Figure 2 and Figure 3 show the plots of the pdf, cdf and hrf for various values of the parameters respectively.

We can derive the mode of the 2SQLindelydistribution by solving the following equation withrespect to *x *as follow;

(8) |

It is not possible to get an explicit solution of the equation (8) in the general case and therefore numerical methods should be used such as bisection method or fixed-point method to solve it.

The r^{th} moment about origin of the 2SQLindely has been obtained as

(9) |

**Proof**: Let us introduce the gamma function defined by By using the pdf of given by (3), we have

The proof of the moments using the QL distribution as a baseline is given below. Let us recall that, for any and a random variable *X* following the QL distribution with parameters and the r^{th} moment of *X* is given by

Therefore, by and the binomial formula, the r^{th} moment of is given by

So, the r^{th} moment will be

Particularly, the mean of *X* is given by and the variance of *X* is given by

Also, the skewness and kurtosis coefficients of *X*, respectively given by

Let *r* be a positive integer and *X* a random variable following the 2SQLindely distribution with parameters and Let us introduce the lower gamma function defined by

Then,

(10) |

**Proof**: By using the pdf of X given by (3), we have

The moment generating function of a random variable is given by

(11) |

**Proof**. Let us recall that, for any and a random variable X following the 2SQLindely distribution with parameters and the moment generating function of X is given by

The characteristic function of distribution is given in the following.

Suppose that the random variable *X* have the then characteristic function, is

(12) |

Where

Bonferroni and Lorenz curve proposed by ^{ 17}. They are used to measure the inequality of the distribution of a random variable X. They are applied in many fields such as economics, reliability, demography, insurance, etc. The Bonferroni and Lorenz curves are defined as

and

respectively, where

If *X* has the pdf in (3), we can calculate Bonferroni and Lorenz curve of the distribution as

(13) |

where

defined in 10

Let us consider a random sample of size n from the 2SQLindely distribution with parameters and Let be the sample minima and be the sample maxima. Then, we have the following limit results

(14) |

In ^{ 18}, they ensure the existence of and such that

We recognize the cdf of the exponential distribution with parameter 1, showing that can be approximated by this distribution.

Moreover, we have

To ensure the existence of and such that

We recognize the cdf of the Gumbel distribution with parameters 1 and showing that can be approximated by this distribution.

Assume be a random sample of size n from then the likelihood function can be written as

(15) |

By accumulation taking logarithm of equation (15), and the log- likelihood function can be written as

(16) |

Maximizing with respect to we have the following system respectively with non-linear equations

(17) |

(18) |

The solution of this system has to be obtained numerically to get the estimates

In this section, we estimate the bias (Bias(.)) and the mean square error (MSE(.)) for the parameters = (1.7,1.5),(0.7,0.5) using simulation study. The population parameter is generated using software “Mathcad 14” package program. The sampling distributions are obtained for different sample sizes n = [20,40, 100, 300, 500] from N= 1000 replications. The simulations results are reported in Table 1 and Table 2.

Here, we use two data sets to illustrate the power of the proposed 2SQLindely distribution. We compare the proposed distribution with the 2SQLindely, QL, Lindley and exponential distributions.

The first real data set is data of survival times (in days) of 72 guinea pigs infected with virulent tubercle bacilli, observed and reported by ^{ 19}.

1, 33, 44, 56, 59, 72, 74, 77, 92, 93, 96, 100, 100, 102, 105,107, 107, 108, 108, 108, 109, 112, 113, 115, 116, 120, 121, 122, 122, 124,130, 134, 136, 139, 144, 146, 153, 159, 160, 163, 163, 168, 171, 172, 176,

183, 195, 196, 197, 202, 213, 215, 216, 222, 230, 231, 240, 245, 251, 253,254, 254, 278, 293, 327, 342,347, 361, 402, 432, 458, 555.

The second real data set represents the waiting times (in minutes) before service of 100 Bank customers and examined and analyzed by ^{ 2}.

0.8, 0.8, 1.3, 1.5, 1.8, 1.9, 1.9, 2.1, 2.6, 2.7, 2.9, 3.1,3.2, 3.3, 3.5, 3.6, 4.0, 4.1, 4.2, 4.2, 4.3, 4.3, 4.4, 4.4, 4.6, 4.7, 4.7, 4.8, 4.9 ,4.9, 5.0, 5.3, 5.5, 5.7, 5.7, 6.1,,6.2, 6.2, 6.2, 6.3, 6.7 ,6.9 ,7.1, 7.1, 7.1, 7.1, 7.4, 7.6, 7.7, 8.0, 8.2, 8.6, 8.6, 8.6, 8.8, 8.8, 8.9, 8.9, 9.5, 9.6,9.7, 9.8, 10.7, 10.9, 11.0, 11.0, 11.1, 11.2, 11.2, 11.5, 11.9, 12.4,12.5, 12.9, 13.0, 13.1, 13.3 , 13.6 , 13.7, 13.9, 14.1, 15.4, 15.4, 17.3,17.3, 18.1, 18.2, 18.4, 18.9, 19.0, 19.9, 20.6, 21.3, 21.4, 21.9, 23.0,27.0, 31.6, 33.1, 38.5

For comparing the goodness of fit of the models, we found the unknown parameters by the maximum likelihood method, -2log likelihood (), AIC (Akaike Information Criterion), BIC (Bayesian Information Criterion), Corrected Akaike Information Criterion (), Kolmogorov-Smirnov(K-S) and Cramérvon Mises statistic, given by

and

Table 3 and Table 4 summarize the results of the Fitted 2SQLindely, QL, Lindley and exponential distributions for the two considered data sets.

From Table 3 and Table 4, it is obvious that the smallest AIC, BIC, CAIA,K-S and statistic are acquired for the 2SQLindely distribution. In summary, we can conclude that the 2SQLindely model can be adequate for modeling these data.

This section is devoted to the difference of two independent random variables following the QL distribution with pdf given by equation (2), 2DQLindely distribution.

Let and be two independent random variables following the QL distribution with parameters and Then, the random variable has the pdf given by :

(19) |

**Proof:** Since the support of and is and the support of X is let us notice that the cdf and pdf of are, respectively, given by

Since and - are independent, the pdf of X is given by the convolution product

When we have implying that

When we have implying that

By putting the above results together, we obtain the desired result.

Like the distribution of the sum of two independent variables, this distribution is considered entirely new as it has not been previously deduced and is considered a generalized distribution for the distribution of the difference between two independent variables for which the Lindley distribution provided by Chesneau, et al (2020). Whereas, through this research and in what part if placed, we obtain the same results as that of Chesneau, et al (2020).

The cdf of the 2DQLindley distribution is given by

(20) |

**Proof**: by using (19), we have

Since the distribution of X is symmetric around 0, for we have

We obtain the desired result by putting the above equalities together.

By using the corresponding survival function is given by

(21) |

The hazard rate function, hrf, is given by

(22) |

Also, the corresponding cumulative hazard rate function, hrf, is given by

(23) |

The corresponding quantile function, say can be obtained by solving the following equation: It cannot be presented analytically but can be determined numerically for a given and

Figure 8, Figure 9 and Figure 10 show the plots of the pdf, cdf and hrf for various values of the parameters respectively.

Let be three random variables following the Laplace distribution with parameter and B a random variable following the Bernoulli distribution with parameter all these random variables are independent. Let X be a random variable following the 2DQLindley distribution with parameters and Then, we have the following stochastic representation:

**Proof**: It is enough to remark that we can write given by (19) as

where

One can notice that is the pdf of the Laplace distribution with parameter r and is the pdf of the sum of two independent random variables both following the Laplace distribution with parameter as common distribution, see, [Kotz, et al (2001) , Section 2.3].

The r^{th} moment about origin of the 2DQLindley has been obtained as

(24) |

**Proof**: Since the distribution of X is symmetric around 0 and the integral is well defined, for any we have By the use of the gamma function, for any we have

By distinguishing the odd and even integer, we can get the proof.

Also, owing to the r^{th} moment, we have

In particular, the mean of X is given by and the variance of X is given by

We can see that the variance of the 2SQLindley and 2DQLindley distributions are the same

The skewness of X is equal to 0 and the kurtosis of X is given by

The moment generating function of a random variable is given by

(25) |

**Proof**. Let us recall that, for any and a random variable X following the QL distribution with parameters and the moment generating function of X is given by

Hence, using the representation with and independent and identically distributed, the characteristic function for X is given by

We can also write themoment generating function as follow,

which is exactly the moment generating function of Which reflect the targeted result.

Suppose that the random variable X have the then characteristic function, is

(26) |

Where

**Proof:**

The proof is simple.

Assume be a random sample of size n from then the likelihood function can be written as

(27) |

By accumulation taking logarithm of equation (27), and the log- likelihood function can be written as

(28) |

Maximizing with respect to we have the following system with non-linear equations

(29) |

(30) |

This equation cannot be solved analytically. However, some numerical algorithm allows to approach the solution in a precise way.

In this section, we estimate the bias (Bias(.)) and the mean square error (MSE(.)) for the parameters = (1.3,1.7),(0.4,0.9) using simulation study. The population parameter is generated using software “Mathcad 14” package program. The sampling distributions are obtained for different sample sizes n = [20,40, 100, 300, 500] from N= 1000 replications. The simulations results are reported in Table 5, Table 6.

In this section, we analyze two data sets in order to illustrate the good performance of the 2DQLindley distribution to compare with the Laplace and 2SLaplace distributions, both with parameters standardly denoted by and Here, we consider an extended form of the 2DQLindley distribution by adding the location parameter in the pdf of the 2DQLindley distribution. Thus, the related pdf is given by

The first data sets correspond to the tensile strength of craft paper, reported in ^{ 20}. The data set are given below:

6.3 11.1 20.0 24.0 26.1 30.0 33.8 34.0 38.1 39.9 42.0 46.1 53.1 52.0 52.5 48.0 42.8 27.8 21.9

The second data set representing lung cancer rates data for 44 US states is given by www.calvin.edu/stob/data/cigs.csv. The data are given below:

17.05 19.8, 15.98 22.07 22.83 24.55 27.27 23.57 13.58 22.8 20.3 16.59 16.84 17.71 25.45 20.94,26.48 22.04 22.72 14.2 15.6 20.98 19.5 16.7 23.03 25.95 14.59 25.02 12.12 21.89,19.45 12.11,23.68 17.45 14.11 17.6 20.74 12.01 21.22 20.34 20.55 15.53 15.92 25.88

Table 7 and Table 8 summarize the results of the Fitted 2DQLindley, Laplace and 2SLaplace distributions for the two considered data sets.

Figure 11, Figure 12, Figure 13 and Figure 14 shown that the smallest AIC, BIC, CAIA,K-S and statistic are acquired for the 2DQLindley distribution. In summary, we can conclude that the 2DQLindley model can be adequate for modeling these data.

In this paper, we have derived single representations for the exact distribution of the sum and difference of independent QL random variables. We referred to the distributions of sum and difference of two independent QL random variables as the 2SQLindely and 2DQLindley distributions, respectively. Statistical properties such as moments, incomplete moments, characteristic function and extreme order statistics of the 2SQLindely distribution have been provided. At the same time, a comprehensive study of statistical properties of the 2DQLindley distribution also has been discussed. The model parameters are estimated by maximum likelihood method for both cases. From simulation studies, the performance of the maximum likelihood estimators has been assessed. The new models provide consistently better fit than some classical models available in the literature. In conclusion, proposed model with their attracting properties should have a promising future in distribution theory.

Finally, we can say this paper is a generalization of the results were obtained in Chesneau, et al (2020) when

The authors thank the anonymous referees for their constructive criticism and valuable suggestions to improve the content of this manuscript.

[1] | Lindley, D. V. (1958). Fiducial distributions and Bayes’ theorem. Journal of the Royal Statistical Society. Series B. (Methodological). 20, 102-107. | ||

In article | View Article | ||

[2] | Ghitany, M.E., Atieh, B. and Nadarajah, S. (2008). Lindley distribution and its Applications, Mathematical Computation and Simulation, 78 (4), 493-506. | ||

In article | View Article | ||

[3] | Zakerzadeh, H. and Dolati, A. (2009). Generalized Lindley distribution, Journal of mathematical extension. 3(2), 13-25. | ||

In article | |||

[4] | Mahmoudi, E. and Zakerzadeh, H. (2010). Generalized Poisson-Lindley distribution, Communications in Statistics - Theory and Methods, 39 (10), 1785-1798. | ||

In article | View Article | ||

[5] | Nadarajah, S., Bakouch, H.S. and Tahmasbi, R. (2011). A generalized Lindley distribution, Sankhya B-Applied and Interdisciplinary Statistics. 73, 331-359. | ||

In article | View Article | ||

[6] | Zakerzadeh, H. and Mahmoudi, E. (2012). A New Two Parameter Lifetime Distribution: Model and Properties, arXiv:1204.4248 [stat.CO], http://arxiv.org/abs/1204.4248. | ||

In article | |||

[7] | Ghitany, M.E., Al-Mutairi, D.K, Balakrishnan, N. and Al-Enezi, L.J. (2013). Power lindley distribution and associated inference, Computational Statistics and Data Analysis, 64, 20-33. | ||

In article | View Article | ||

[8] | Shanker, R. and Mishra, A. (2013a). A two-parameter Lindley distribution, Statistics in transition new series, 14(1), 45-56. | ||

In article | |||

[9] | Shanker, R. and Mishra, A. (2013b). A quasi Lindley distribution, African Journal of Mathematics and Computer Science Research. 6(4), 64-71. | ||

In article | |||

[10] | Merovci, F. and Elbatal, I. (2014). Transmuted Lindley-geometric distribution and its applications, Journal of Statistics Applications and Probability. 3, 77-91. | ||

In article | View Article | ||

[11] | Merovci, F. and Sharma, V.K. (2014). The beta Lindley distribution: Properties and applications, Journal of applied mathematics, 2014, Article ID 198951. | ||

In article | View Article | ||

[12] | Tomy, L. (2018). A retrospective study on Lindley distribution, Biometrics and Biostatistics International Journal. 7(3), 163-169. | ||

In article | View Article | ||

[13] | Thomas S.P., Jose K.K. and Tomy, L. (2019). Discrete Harris Extended Lindley Distribution and Applications, preprint. | ||

In article | |||

[14] | Chesneau, C., Tomy, L. and Gillariose, J. (2019). A new modified Lindley distribution with properties and applications, preprint. | ||

In article | View Article | ||

[15] | Chesneau. C, Tomy. L and Gillariose. J, (2020), On a Sum and Difference of two Lindley distributions: theory and applications, Revstat, 18 (5), 673-695. | ||

In article | |||

[16] | Kotz, S., Kozubowski, T.J. and Podgorski, K. (2001). The Laplace Distribution and Generalizations. A Revisit with Applications to Communications, Economics, Engineering and Finance. Boston: Birkhäuser. | ||

In article | View Article | ||

[17] | Bonferroni, C.E. (1930), Elementi di Statistca generale, Seeber, Firenze. | ||

In article | |||

[18] | Leadbetter, M.R., Lindgren, G. and Rootzén H. (1987). Extremes and related properties of random sequences and processes. New York, Springer Verlag. | ||

In article | |||

[19] | Bjerkedal T. (1960). Acquisition of resistance in guinea pigs infected with different doses of virulent tubercle bacilli. Am J Hyg, 72, 130-148. | ||

In article | View Article PubMed | ||

[20] | Montgomery, D.C., Peck, E.A. and Vining, G.G. (2015). Introduction to Linear Regression Analysis, John Wiley and Sons. | ||

In article | |||

Published with license by Science and Education Publishing, Copyright © 2021 Yasser M. Amer, Dina H. Abdel Hady and Rania M. Shalabi

This work is licensed under a Creative Commons Attribution 4.0 International License. To view a copy of this license, visit http://creativecommons.org/licenses/by/4.0/

Yasser M. Amer, Dina H. Abdel Hady, Rania M. Shalabi. On a Sum and Difference of Two Quasi Lindley Distributions: Theory and Applications. *American Journal of Applied Mathematics and Statistics*. Vol. 9, No. 1, 2021, pp 12-23. http://pubs.sciepub.com/ajams/9/1/3

Amer, Yasser M., Dina H. Abdel Hady, and Rania M. Shalabi. "On a Sum and Difference of Two Quasi Lindley Distributions: Theory and Applications." *American Journal of Applied Mathematics and Statistics* 9.1 (2021): 12-23.

Amer, Y. M. , Hady, D. H. A. , & Shalabi, R. M. (2021). On a Sum and Difference of Two Quasi Lindley Distributions: Theory and Applications. *American Journal of Applied Mathematics and Statistics*, *9*(1), 12-23.

Amer, Yasser M., Dina H. Abdel Hady, and Rania M. Shalabi. "On a Sum and Difference of Two Quasi Lindley Distributions: Theory and Applications." *American Journal of Applied Mathematics and Statistics* 9, no. 1 (2021): 12-23.

Share

[1] | Lindley, D. V. (1958). Fiducial distributions and Bayes’ theorem. Journal of the Royal Statistical Society. Series B. (Methodological). 20, 102-107. | ||

In article | View Article | ||

[2] | Ghitany, M.E., Atieh, B. and Nadarajah, S. (2008). Lindley distribution and its Applications, Mathematical Computation and Simulation, 78 (4), 493-506. | ||

In article | View Article | ||

[3] | Zakerzadeh, H. and Dolati, A. (2009). Generalized Lindley distribution, Journal of mathematical extension. 3(2), 13-25. | ||

In article | |||

[4] | Mahmoudi, E. and Zakerzadeh, H. (2010). Generalized Poisson-Lindley distribution, Communications in Statistics - Theory and Methods, 39 (10), 1785-1798. | ||

In article | View Article | ||

[5] | Nadarajah, S., Bakouch, H.S. and Tahmasbi, R. (2011). A generalized Lindley distribution, Sankhya B-Applied and Interdisciplinary Statistics. 73, 331-359. | ||

In article | View Article | ||

[6] | Zakerzadeh, H. and Mahmoudi, E. (2012). A New Two Parameter Lifetime Distribution: Model and Properties, arXiv:1204.4248 [stat.CO], http://arxiv.org/abs/1204.4248. | ||

In article | |||

[7] | Ghitany, M.E., Al-Mutairi, D.K, Balakrishnan, N. and Al-Enezi, L.J. (2013). Power lindley distribution and associated inference, Computational Statistics and Data Analysis, 64, 20-33. | ||

In article | View Article | ||

[8] | Shanker, R. and Mishra, A. (2013a). A two-parameter Lindley distribution, Statistics in transition new series, 14(1), 45-56. | ||

In article | |||

[9] | Shanker, R. and Mishra, A. (2013b). A quasi Lindley distribution, African Journal of Mathematics and Computer Science Research. 6(4), 64-71. | ||

In article | |||

[10] | Merovci, F. and Elbatal, I. (2014). Transmuted Lindley-geometric distribution and its applications, Journal of Statistics Applications and Probability. 3, 77-91. | ||

In article | View Article | ||

[11] | Merovci, F. and Sharma, V.K. (2014). The beta Lindley distribution: Properties and applications, Journal of applied mathematics, 2014, Article ID 198951. | ||

In article | View Article | ||

[12] | Tomy, L. (2018). A retrospective study on Lindley distribution, Biometrics and Biostatistics International Journal. 7(3), 163-169. | ||

In article | View Article | ||

[13] | Thomas S.P., Jose K.K. and Tomy, L. (2019). Discrete Harris Extended Lindley Distribution and Applications, preprint. | ||

In article | |||

[14] | Chesneau, C., Tomy, L. and Gillariose, J. (2019). A new modified Lindley distribution with properties and applications, preprint. | ||

In article | View Article | ||

[15] | Chesneau. C, Tomy. L and Gillariose. J, (2020), On a Sum and Difference of two Lindley distributions: theory and applications, Revstat, 18 (5), 673-695. | ||

In article | |||

[16] | Kotz, S., Kozubowski, T.J. and Podgorski, K. (2001). The Laplace Distribution and Generalizations. A Revisit with Applications to Communications, Economics, Engineering and Finance. Boston: Birkhäuser. | ||

In article | View Article | ||

[17] | Bonferroni, C.E. (1930), Elementi di Statistca generale, Seeber, Firenze. | ||

In article | |||

[18] | Leadbetter, M.R., Lindgren, G. and Rootzén H. (1987). Extremes and related properties of random sequences and processes. New York, Springer Verlag. | ||

In article | |||

[19] | Bjerkedal T. (1960). Acquisition of resistance in guinea pigs infected with different doses of virulent tubercle bacilli. Am J Hyg, 72, 130-148. | ||

In article | View Article PubMed | ||

[20] | Montgomery, D.C., Peck, E.A. and Vining, G.G. (2015). Introduction to Linear Regression Analysis, John Wiley and Sons. | ||

In article | |||