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Optimal Threshold Determination for the Maximum Product of Spacing Methodology with Ties for Extreme Events

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^{1}Department of Mathematics, Masinde Muliro University of Science and Technology, Kakamega, Western Province, Kenya.

^{2}Department of Statistics and Actuarial Science, Jomo Kenyatta University of Agriculture and Technology, Nairobi, Kenya.

^{3}Mainde Muliro University of Science and Technology, Kakamega Western Province, Kenya.

KEYWORDS

1. Introduction

Certain values in the tails of any distribution, represent extreme events and they are pointers to eventuality. The values in the tails are rare, few, but can have great impact on the conclusion arrived at by the analysts. Different sectors of our life experience extreme events and here we mention just but a few. According to [1] and [2] , extremely low production in agriculture results to famine if the agriculture depends on rainfall. This means that the amount of rain experienced in that region was too low that crops dried up [3] or very high rainfall that it destroyed all crops that had been planted. [4] studying extreme rainfall in mountainous region and [5] studying extreme rainfall in west Africa did observe that, how low or high the amount of rainfall depends on the threshold attached to the rainfall in that region. In insurance industries [6] , while discussing tools in finance and insurance, noted that extreme high claims by the customers can be very dangerous for the company while extreme low claims by the customers can be very beneficial for the company’s profit. This means that there is a critical level that the insurance company would wish it is not surpassed and if it is, according to [7] , it must be prepared for this eventuality. Very high emissions of the waste product from the manufacturing industries is detrimental to the environment and ozone layer. However, countries must continue to industrialize or expand their industries for economic prosperity. A certain level of emissions must not be exceeded otherwise the environment and ozone layer would be destroyed. The critical value for which if exceeded, an eventuality occurs is called a threshold. The events beyond this threshold are called extreme events and they happen to be at the tails of the distribution. Extreme value theory (EVT) is a tool which attempts to provide us with the best possible estimate of the tail area of the distribution. In [8] work on the importance of tail dependence in Bivariate frequency analysis, there are two principal kinds of model for extreme values. The oldest group of models is the block maxima models; these are models for the largest observations collected from large samples of identically distributed observations. According to [9] and [10] , the block maxima/minima methods are fitted with the generalized extreme value (GEV) distribution. A more modern group of models is the peaks-over-threshold (POT) models; these are models for all large observations which exceed a high threshold. The POT models are generally considered to be the most useful for practical applications, due to a number of reasons. First, by taking all exceedances over a suitably high threshold into account, they use the data more efficiently and second, they are easily extended to situations where one wants to study how the extreme levels of a variable Y depend on some other variable X for instance, Y may be the level of tropospheric ozone on a particular day and X a vector of meteorological variables for that day. This kind of problem is almost impossible to handle through the annual maxima/minima method. POT methods are used where the exceedances are modeled to understand the behavior of the data in the tails. Many methods of determining an optimal threshold have been developed. The most common one is the graphical method proposed by [11] . This method is however subjective and requires experts to determine the threshold. The most successful method is the Maximum Product of Spacing (MPS). Maximum product of spacing (MPS) method or maximum spacing estimation (MSE) method was proposed by Cheng [12] and Ramnaby [13] as an alternative method to maximum Likelihood Estimate method (MLE). A threshold approach for peaks over threshold using MPS was carried out by [14] and noted that the selection of a threshold is an important and challenging problem [15] . While studying traditional estimation methods and MPS in Generalized Inverted Exponential Distribution found out that MPS outperformed MLE and least square (LSE) methods on the basis of K-S distance and Akaike Information Criterion (AIC). This method however encounters a problem whenever the exceedances have a tie. This study intended to offer a solution to this problem.

2. Methodology

2.1. Improved MPS Methodology

The MPS allows efficient estimators in non regular cases where MLE may not exist. This is especially relevant to the GEV distribution in which the MLE does not exist when $\epsilon <-1$ . According to [12] Maximum spacing estimators are sensitive to closely spaced observations, and especially ties. In cases of ties, some scholars have suggested that one value of each tie is taken [16] and [17] . Let ${x}_{1},{x}_{2},\cdots ,{x}_{n}$ be a random sample of independent observations from a continuous distribution ${F}_{{\theta}_{0}}$ belonging to ${F}_{\theta}\mathrm{,}\theta \in \Theta $ . Applying the probability transform ${F}_{\theta}\left(\mathrm{.}\right)$ to the order statistics ${x}_{\mathrm{1,}n}\le {x}_{\mathrm{2,}n}\le \cdots \le {x}_{n\mathrm{,}n}$ yields $0\equiv {F}_{\theta}\left({x}_{\mathrm{0,}n}\right)\le {F}_{\theta}\left({x}_{\mathrm{1,}n}\right)\le \cdots \le {F}_{\theta}\left({x}_{n+\mathrm{1,}n}\right)\equiv 1$ . We define the spacings as the gaps between the values of the distribution function at adjacent ordered points

${D}_{i}\left(\theta \right)={F}_{\theta}\left({x}_{i}\right)-{F}_{\theta}\left({x}_{i-1}\right)\text{\hspace{0.05em}}$ (1)

for $i=1,2,\cdots ,n+1$ . The maximum spacing estimator of ${\theta}_{0}$ was defined as value that maximizes the logarithm of the geometric mean of sample spacings [12] .

$\stackrel{^}{\theta}=\underset{\theta \in \Theta}{\mathrm{arg}\mathrm{max}}{S}_{n}\left(\theta \right)$ (2)

where

$\begin{array}{c}{S}_{n}\left(\theta \right)=\mathrm{ln}\sqrt[n+1]{\left({D}_{1}\left(\theta \right)\cdot {D}_{2}\left(\theta \right)\cdots {D}_{n+1}\left(\theta \right)\right)}\\ =\frac{1}{n+1}{\displaystyle \underset{i=1}{\overset{n+1}{\sum}}}\mathrm{ln}{D}_{i}(\theta )\end{array}$

This maximum spacing estimator is sensitive to the ties. That is, for any

${x}_{i+m}={x}_{i+m-1}=\cdots ={x}_{i}$

Then ${D}_{i+m}\left(\theta \right)={D}_{i+m-1}\left(\theta \right)=\cdots ={D}_{i}\left(\theta \right)$ . This therefore collapses the method. The modified MPS method proposed here is to use grouped data frequency table. Let ${x}_{1}\mathrm{,}{x}_{2}\mathrm{,}\cdots \mathrm{,}{x}_{n}$ occur ${f}_{1}\mathrm{,}{f}_{2}\mathrm{,}\cdots \mathrm{,}{f}_{n}$ times respectively. The geometric mean is given by

$G={\left({x}_{1}^{{f}_{1}}\cdot {x}_{2}^{{f}_{2}}\cdots {x}_{n}^{{f}_{n}}\right)}^{\frac{1}{N}}={\left[{\displaystyle \underset{i=1}{\overset{n}{\prod}}}\text{\hspace{0.05em}}{x}_{i}^{{f}_{i}}\right]}^{\frac{1}{N}}$

This implies that

$\mathrm{ln}G=\frac{1}{N}{\displaystyle \underset{i=1}{\overset{n}{\sum}}}\text{\hspace{0.05em}}{f}_{i}\mathrm{ln}{x}_{i}$ (3)

This leads to the modified MPS method as

${S}_{n}\left(\theta \right)=\mathrm{ln}\sqrt[n+1]{\left({D}_{1}^{{f}_{1}}\left(\theta \right)\cdot {D}_{2}^{{f}_{2}}\left(\theta \right)\cdots {D}_{n+1}^{{f}_{n+1}}\left(\theta \right)\right)}=\frac{1}{n+1}{\displaystyle \underset{i=1}{\overset{n+1}{\sum}}}\text{\hspace{0.05em}}{f}_{i}\mathrm{ln}{D}_{i}\left(\theta \right)$ (4)

In case ${f}_{1}={f}_{2}=\cdots ={f}_{n+1}=1$ , then we go back to the standard MPS. The Spacings are such that $\underset{i=1}{\overset{n}{\sum}}}\text{\hspace{0.05em}}{D}_{i}\left(\theta \right)=1$ . Under MPS, the ${D}_{i}\left(\theta \right)$ ’s are defined as:

${D}_{1}\left(\theta \right)=F\left({x}_{1:n},\theta \right)$

${D}_{i}\left(\theta \right)=F\left({x}_{i:n},\theta \right)-F\left({x}_{i-1:n},\theta \right)$

${D}_{n+1}\left(\theta \right)=1-F\left({x}_{n:n},\theta \right)$

Therefore, Equation (4) can be partitioned as:

${S}_{n}\left({x}_{i};\theta ,\epsilon ,\sigma \right)=\frac{1}{n+1}\left\{{f}_{1}\mathrm{ln}{D}_{1}\left(\theta \right)+{\displaystyle \underset{i=2}{\overset{n}{\sum}}}\text{\hspace{0.05em}}{f}_{i}\mathrm{ln}{D}_{i}\left(\theta \right)+{f}_{n+1}\mathrm{ln}{D}_{n+1}\left(\theta \right)\right\}$ (5)

2.2. Estimation of Generalized Pareto Distribution Using the Modified MPS Method

To estimate the parameters, we substitute the GPD

$G\left(x;\epsilon ,\sigma \right)=\{\begin{array}{l}1-{\left[1+\epsilon \left(\frac{x-u}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}},\text{\hspace{0.17em}}\text{\hspace{0.17em}}\epsilon \ne 0\\ 1-\mathrm{exp}\left[-\left(\frac{x-u}{\sigma}\right)\right],\text{\hspace{0.05em}}\text{\hspace{0.05em}}\text{\hspace{0.05em}}\text{\hspace{0.05em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\epsilon =0\end{array}$ (6)

into the MPS method. This lead to two cases of estimating the GPD parameters.

2.2.1. Case 1: When $\epsilon \ne 0$

In this case:

${D}_{1}=1-{\left[1+\epsilon \left(\frac{{x}_{1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}$ (7)

${D}_{i}=\left(1-{\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right)-\left(1-{\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right)$

which leads to

${D}_{i}={\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}-{\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}$ (8)

and

${D}_{n+1}=1-\left(1-{\left[1+\epsilon \left(\frac{{x}_{n}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right)$ (9)

implying that

${D}_{n+1}={\left[1+\epsilon \left(\frac{{x}_{n}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}$

Therefore, Equation (5) now becomes:

$\begin{array}{c}{S}_{n}\left({x}_{i};\theta ,\epsilon ,\sigma \right)=\frac{1}{n+1}\{{f}_{1}\mathrm{ln}\left(1-{\left[1+\epsilon \left(\frac{{x}_{1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right)\\ \text{\hspace{0.17em}}\text{\hspace{0.17em}}+{\displaystyle \underset{i=2}{\overset{n}{\sum}}}\text{\hspace{0.05em}}\text{\hspace{0.05em}}{f}_{i}\mathrm{ln}\left({\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}-{\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right)\\ \text{\hspace{0.17em}}\text{\hspace{0.17em}}+{f}_{n+1}\mathrm{ln}{\left[1+\epsilon \left(\frac{{x}_{n}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\}\end{array}$ (10)

The estimation of the parameters involves taking partial derivatives of Equation (10) with respect to each of the parameters and setting the result to zero. For the estimation of $\epsilon $ , the first term on the R.H.S is worked out as:

Let

${K}_{1}=\mathrm{ln}\left(1-{\left[1+\epsilon \left(\frac{{x}_{1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right)$ (11)

implying that

$\frac{\partial {K}_{1}}{\partial \epsilon}=\frac{\left({x}_{1}-\theta \right)}{\sigma \epsilon \left(1+\epsilon \left(\frac{{x}_{1}-\theta}{\sigma}\right)\right)}-\frac{1}{{\epsilon}^{2}}\mathrm{ln}\left(1+\epsilon \left(\frac{{x}_{1}-\theta}{\sigma}\right)\right)$ (12)

Working out the second term of Equation (10);

Let

${K}_{2}=\mathrm{ln}\left\{{\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}-{\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right\}$ (13)

Therefore;

$\begin{array}{c}\frac{\partial {K}_{2}}{\partial \epsilon}=\left(\frac{1}{{\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}-{\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}}\right)\\ \text{\hspace{0.17em}}\text{\hspace{0.17em}}\times \{\left(\frac{1}{{\epsilon}^{2}}\mathrm{ln}\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]-\frac{1}{\epsilon}\times \frac{1}{1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)}\times \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right)\\ \text{\hspace{0.17em}}\text{\hspace{0.17em}}-\left(\frac{1}{{\epsilon}^{2}}\mathrm{ln}\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]-\frac{1}{\epsilon}\times \frac{1}{1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)}\times \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right)\}\end{array}$ (14)

And the last term of Equation (10);

Let

${K}_{3}=\mathrm{ln}{\left[1+\epsilon \left(\frac{{x}_{n}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}$ (15)

Therefore,

$\frac{\partial {K}_{3}}{\partial \epsilon}=\left(\frac{1}{{\left[1+\epsilon \left(\frac{{x}_{n}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}}\right)\left\{\frac{1}{{\epsilon}^{2}}\mathrm{ln}\left[1+\epsilon \left(\frac{{x}_{n}-\theta}{\sigma}\right)\right]-\frac{1}{\epsilon}\left(\frac{{x}_{n}-\theta}{\sigma}\right)\right\}$ (16)

Similarly, we parameter to estimate is $\sigma $ , from the:

$\frac{\partial {K}_{1}}{\partial \sigma}=\frac{1}{\left[1-{\left[1+\epsilon \left(\frac{{x}_{1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}\right]}\left[{\left[1+\epsilon \left(\frac{{x}_{1}-\theta}{\sigma}\right)\right]}^{-\frac{\left(1+\epsilon \right)}{\epsilon}}\right]\times \left(\frac{{x}_{1}-\theta}{{\sigma}^{2}}\right)$ (17)

$\frac{\partial {K}_{2}}{\partial \sigma}=\frac{\partial {K}_{2}}{\partial w}\times \frac{\partial w}{\partial \sigma}$

$\begin{array}{l}\frac{\partial {K}_{2}}{\partial \sigma}=\frac{1}{{\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}-{\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]}^{-\frac{1}{\epsilon}}}\\ \text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\times \{\left(\frac{{x}_{i}-\theta}{{\sigma}^{2}}\right){\left[1+\epsilon \left(\frac{{x}_{i}-\theta}{\sigma}\right)\right]}^{-\frac{\left(1+\epsilon \right)}{\epsilon}}\\ \text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}-\left(\frac{{x}_{i-1}-\theta}{{\sigma}^{2}}\right){\left[1+\epsilon \left(\frac{{x}_{i-1}-\theta}{\sigma}\right)\right]}^{-\frac{\left(1+\epsilon \right)}{\epsilon}}\}\end{array}$ (18)

and

$\frac{\partial {K}_{3}}{\partial \sigma}=-\left(\frac{{x}_{n}-\theta}{{\sigma}^{2}}\right){\left[1+\epsilon \left(\frac{{x}_{n}-\theta}{\sigma}\right)\right]}^{-1}$ (19)

Finally, we estimate as follows:

(20)

(21)

and

(22)

Therefore, after differentiating partially Equation (10) with respect to the parameters, we get the normal Equations (23), (24) and (25);

(23)

where the terms, and are from Equations (12), (14) and (16) respectively.

(24)

where the terms, and are from Equations (17), (18) and (19) respectively.

(25)

where the terms, and are from Equations (20), (21) and (22) respectively. The parameters were obtained from Equations (23), (24) and (25) using numerical analysis procedures for optimization.

2.2.2. Case 2: When

Parameters under this case are estimated here. When, the spacings become;

(26)

(27)

(28)

Therefore, Equation (5) can be written as;

(29)

Let

(30)

Therefore,

(31)

Similarly, let and

(32)

Therefore,

(33)

Let

(34)

implying that;

(35)

The equations for estimating can also be derived from,

(36)

Next, let and P be defined as Equation (32), so that

Simplifying to;

(37)

Lastly, let be defined as Equation (15), implying that;

(38)

Therefore, after differentiating partially Equation (29) with respect to the parameters, we get the normal Equations (39) and (40);

(39)

where the terms, and are from Equations (31), (33) and (35) respectively.

(40)

where the terms, and are from Equations (36), (37) and (38) respectively. The parameters were obtained from Equations (39) and (40) using numerical analysis procedures for optimization.

3. Results and Discussion

3.1. Simulation Study

A simulation was performed to compare the standard MPS methodology with the improved MPS methodology. We simulated data from a gamma distribution with the parameters shape = 2.6, scale = 1:1000. Repetitions were later introduced in the order of 0, 20, 40 and 60. The repeated values gave rise to situations of ties. Gamma distribution is known to have fairly heavy tails. To determine our threshold, we simulated a set of data constituting 300 values. 100 values did not have a repetition while 100 values had each a repetition making them to have a frequency of 2 each. This set of data was used in the improved MPS model. After the simulation, this set of data was reorganized in such a way that the 300 values had a frequency of 1 each regardless of whether it was repeated or not. This set of data was used in the standard MPS model. The normal equations derived above were used as the model for the improved MPS methodology. For the three parameter models 23, 24 and 25 were used while for two-parameter model 39 and 40 were used.

Suitable values for k and for which the gamma distribution would produce long tail were selected. In this case, a simulation using and was made and the density of the simulation is shown in Figure 1.

The x-axis of Figure 1 represents the number of values generated for the specified parameters of gamma distribution. The y-axis represents the density of those values. Figure 1 indicates that majority of the values are concentrated

Figure 1. The density of the Gamma distributed initial values.

between 0 and 450. The values with big magnitude concentrate to the right of the distribution. The simulated values are Gamma distributed with a long right tail.

When the two parameter standard and improved models were used, the following results Table 1 from the simulation were obtained.

The threshold (location parameter) from the improved MPS model was higher than that obtained through standard MPS model Table 1. However the scale parameter of the improved MPS model was lower than that obtained through the standard MPS model. Three parameter improved MPS model and the standard MPS model were used to determine the threshold of the same data set. The results are shown in Table 2.

The threshold (location parameter) determined from the improved MPS model was high compared to the threshold determined through the standard MPS model Table 2. The shape parameter determined through the improved MPS model was also high compared to the one obtained through the standard MPS model. However, the scale parameter obtained through the improved MPS model was lower than that obtained through the standard MPS model. To assess the performance of the parameters in the standard and improved models,the GPD parameters determined in Table 1 and Table 2 were backtested in the simulated data. Table 3 contains a summary of the values obtained.

From Table 1, a threshold of 725.5767 was determined for the standard MPS model from a data that contained ties. When this threshold was backtested on the same data, It produced 18 data values as excesses Table 3. This was a proportion of 0.06. A threshold of 736.476 was determined for the improved MPS model from the same data that contained ties Table 1. When this threshold was

Table 1. Pars estimates of two parameter model.

Table 2. Pars estimates of three parameter model.

Table 3. Model selection.

backtested, it produced excesses of 15 data values which was a proportion of 0.05 Table 3. The threshold from improved model was higher than that of standard MPS model hence fewer data values in the excesses. The deviance and AIC criterion were used to compare the threshold that would make a generalized pareto distribution (GPD) model more fitting Table 3. The deviance of the two parameter standard MPS model was 214.8238 while that of the two parameter improved MPS model was 183.1161. The deviance of the improved model was lower than that of the standard MPS model. The AIC value of the standard MPS model was 216.8238 while that of the improved MPS model was 185.1161. The improved model had a lower AIC value. Treating the GPD model of the standard MPS model and that of improved MPS model as competing models, then the improved MPS model produced a more optimal threshold than that of standard MPS model. A threshold value of 726.3707 was determined for the three parameter standard model while that for the improved MPS model was 738.1303 Table 2. These two thresholds were back tested in the appropriate data sets Table 3. 18 excesses were realized on backtesting 726.3707 while 15 excesses were realized on back testing the value of 738.1303. The deviance of the standard model was 214.5401 while that of the improved model was 182.7789. The deviance of the improved MPS model was lower than that of the standard model. The AIC value of the improved model is lower than that of the standard MPS model. Whenever two models are competing, the model with the lower AIC is a better model. Thus the threshold obtained from improved MPS model makes the GPD to perform better than that obtained from a standard MPS.

3.2. Effects of Number of Repetitions on Threshold

In this section, the effect of number of repetitions on threshold was investigated. The gamma distribution with parameters and was used. However, to change the number of repetitions, y_{1} and y_{2} were made to take different values. To create a sample with 20 repetitions, variables and were used .To create a sample with 40 repetitions,variables and were used, while a sample of 60 repetitions was created by using the variables and. For 0 repetions, the variables used were

The repetitions cause ties and therefore, these samples contain grouped ties. The improved MPS model used this raw sample. For this sample to be used with standard MPS model, the data had to be ungrouped so as each value had a frequency of one. The density of the distribution in the four cases of repetitions were ploted as shown in Figure 2.

The x-axis of the plots in Figure 2 represents the number of the values specified in the gamma function while the y-axis represents the density of those values for different repetitions. The figure shows that there were some values in the tail and that the distribution was skewed towards right. This distribution was similar to Gamma density which was used in the simulation of this data set. The data indicate that several values are in the tails of the distribution meaning that the density’s contained extreme values. This justified the use of GPD to analyze the simulated data.

According to [16] , some values of each tie have to be dropped to leave only one value of each tie for the standard MPS to work. Therefore, samples of size 300 with ungrouped ties of 0, 20, 40 and 60 repetitions were each subjected to the two parameter standard MPS model. The results obtained were as in Table 4. The threshold (location) value increased as ties increased. However, the scale parameter increased from 5.993496 to 9.99465 then decreased as the number of ties increased. The samples with grouped ties were subjected to the two parameter improved MPS model and the results obtained are as in Table 5. It was observed that, the location parameter(threshold value) increased as the number of ties increased. The scale parameter increased from 4.097801 to

Table 4. Two parameter std model estimates.

Table 5. Two parameter improved model estimates.

Figure 2. The densities for data with repetitions.

7.830554 then decreased as the number of ties increased. The samples with ungrouped ties were subjected to a three parameter standard MPS model and the results are as in Table 6. The location (threshold value) parameter increased from 1111.473 to 1121.675 as the number of ties increased.The scale decreased from 17.44149 to 4.950339. The shape also decreased from −0.05918 to −6.59819 as ties increased. The samples with grouped ties were subjected to the three parameter improved MPS model and the results are as in Table 7. The location (threshold value) parameter increased from 1111.954 to 1141.156 as the number of ties increased from 0 to 60. The scale parameter decreased from 15.4904 to 9.42994 as the number of ties increased from 0 to 60. The shape parameter increased from 0.05365 to 2.54892 at 40 repetitions then decreased to −4.74385 at 60 repetitions.

Plots to compare the performance of the parameters obtained were made as indicated in Figures 3-7.

Figure 3. Behavior of location parameter in the two parameter model.

Figure 4. Behavior of location parameter in the three parameter model.

Table 6. Three parameter standard model estimates.

Figure 5. Behavior of scale parameter in the two parameter model.

Figure 6. Behavior of scale parameter in the three parameter model.

Figure 7. Behavior of shape parameter in the three parameter model.

Table 7. Three parameter improved model estimates.

3.3. Location Parameter

When there was no tie Figure 3, the two parameter standard MPS model and the improved two parameter MPS model give the same threshold. The plot for the two parameter models indicate that the threshold improved as the number of repetitions increased. The increase rate of the improved MPS model was higher than that of the standard MPS model. In both models, there was a decrease of the threshold at around 32 repetitions after which the threshold continued to improve.

The trend observed in the two parameter model Figure 3 was also observed in the performance of the three parameter models Figure 4. However, the drop at 32 repetitions in the three parameter models was not as big as in the two parameter models. From the two plots above, the improved MPS model performed better than the standard MPS models as ties increased.

3.4. Scale Parameter

A plot of scales was also made to compare the performance of the scale parameter as the number of repetitions increased for the two and three parameter MPS model Figure 5.

The two parameter model had different scale parameters when there were no ties. The scale of the standard MPS model increased faster than that of the improved MPS model as the repetitions increased up to the 20 repetitions after which the two models showed a downward trend Figure 5. However, the downward trend rate is higher in the standard MPS model than the improved MPS model. The two models had the same scale parameter at the 31 repetitions. Beyond 31 repetition, the improved model had a higher scale parameter than standard model despite the fact that both of them were still on the decline.

The three parameter MPS models Figure 6 had different scale parameters at zero repetitions. The size of the parameters showed a downward trend but the improved MPS model had a higher rate of downward trend than the standard MPS model up to 20 repetitions after which the trend of the improved MPS model changed and showed some improvements. However the trend of the standard MPS model continued to drop until the 45 repetitions after which it started to improve.The two models had the same scale parameter at about 31 repetitions. The improved MPS model had a higher rate of improvement than the standard one. The trend of the scale parameter in the two parameter model and the three parameter model are similar.

3.5. Shape Parameter

The two parameter standard and improved model have location and scale parameters only. These models have a zero shape parameter. For the three parameter standard and improved models, the shape parameter performed as shown in Figure 7.

The two models had the same shape parameter when the data had no repetitions(ties) 7. The shape parameter of the improved MPS model improved up to around 38 repetitions after which it showed a downward trend. The standard model remained steady between 0 and 20 repetitions after which it followed a downward trend. The drop rate in the shape parameter was higher on improved model than it was on the standard model. The shape parameter showed a consistent decrease beyond 20 repetitions for the standard model and 38 repetitions for the improved model. A general observation was that there was a change in the trend of all parameters in between 30 and 40 repetitions.

3.6. Back Testing Two Parameter Models

The determined threshold obtained in different samples were back tested in the sample data they were obtained from to assess their performance.

For two parameter models at 0 repetitions, both models, the standard and the improved MPS model Table 8, had the same number of observations over the threshold and both had the same deviance value and AIC criterion value. Therefore, at this level both models performance were the same. At 20 repetitions, the standard model had 23 observations over the threshold while the improved model had 21 observations over the threshold. However, the deviance value and AIC criterion values were lower in the case of improved model compared to those of the standard model. For 40 repetitions, the number above the threshold was 14 for both models but the deviance value and AIC criterion values of the improved model were lower compared to those criterion values for improved model were lower than those of standard model. From this analysis, the improved MPS model performed better than the standard MPS model.

Table 8. Two Parameter model with repetitions.

Table 9. Three parameter model with repetitions.

3.7. Back Testing Three Parameter Model

To assess the performance of the threshold obtained when the GPD had the shape parameter,a back testing was done on the samples through the two models and the results were as in Table 9.

For 0 repetitions, the number of observations above the threshold were 16 in both models Table 9. The deviance values and the AIC values were the same for the three parameter model. Meaning that the two models performed equally the same. For 20 repetitions, the number of observations were 21 but the deviance value and AIC criterion value were lower in case of improved model compared to those of standard model. The deviance value and AIC criterion value for the improved model were also lower than those of standard model in the 40 and 60 repetitions although, the number of observations in the 40 repetitions were 14 while that of the 60 repetitions were 11. In this case therefore, the improved model performed better than the standard model. The presence of ties in the data set causes a difference in the performance of the two models.

4. Conclusion

This study helped to improve the MPS model by introducing the concept of f to both two-parameter and three-parameter model 23, 24, 25, 39 and 40. Through simulation, the improved MPS, both two-parameter and three-parameter models yielded a higher threshold as compared to the two standard MPS model Table 1 and Table 2. The scale parameter of the improved MPS model was lower than that of the standard model. The shape parameter of the improved model performed well compared to the standard model. When the determined GPD parameters were back tested into the same simulated data Table 3, the improved model performed better than the standard model. The deviance statistics and the AIC criterion for the improved model yielded lower values compared to the standard model. This study therefore managed to come up with an improved MPS model which was able to take care of the analysis of ties in the data set. The back testing for each repetition indicates that the improved MPS model performed better than the standard MPS model. When frequency of each data point, the improved MPS model reduces to the standard model. The improved MPS model helps to yield a more optimal threshold which in turn would help different sectors of the country’s economy to be adequately prepared for any eventuality.

Conflicts of Interest

The authors declare no conflicts of interest regarding the publication of this paper.

Cite this paper

*Open Journal of Modelling and Simulation*,

**7**, 149-168. doi: 10.4236/ojmsi.2019.73008.

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