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A Simple but Efficient Approach for Testing Fuzzy Hypotheses
Journal of Uncertainty Analysis and Applications volume 4, Article number: 2 (2016)
Abstract
In this paper, a new method is proposed for testing fuzzy hypotheses based on the following two generalized pvalues: (1) the generalized pvalue of null fuzzy hypothesis against alternative fuzzy hypothesis and (2) the generalized pvalue of alternative fuzzy hypothesis against null fuzzy hypothesis. In the proposed method, each generalized pvalue is formulated on the basis of Zadeh’s probability measure of fuzzy events. The introduced pvalue method has several advantages over the common pvalue methods for testing fuzzy hypotheses. A few illustrative examples and also an agricultural example, based on a realworld data set, are given to clarify the proposed method.
Introduction
After the inception of the concept of fuzzy set by Zadeh [23], many statistitions have extended different methods of testing statistical hypotheses using the fuzzy set theory, e.g. see [3, 4, 18, 19]. Beside the mentioned works on testing hypothesis in fuzzy environment, some works have been done by researchers based on the concept of pvalue. Filzmoser and Viertl [8] worked on the problem of testing hypotheses and introduced a fuzzy pvalue when the observations are fuzzy and hypotheses are crisp, also see [6, 21]. For instance, when the form of the rejection region is T≥t _{ r }, the δ cut of their proposed fuzzy pvalue is
in which θ _{0} is the boundary of null hypothesis and \( \tilde {t}_{\delta }=\left [t_{1}(\delta),t_{2}(\delta) \right ] \) is the δ cut of the test statistic.
Using the extension principle, Parchami et al. [14] discussed on testing fuzzy hypotheses with crisp data and introduced the concept of the fuzzy pvalue for such situations. For instance, when the form of the rejection region is T≥t _{ r }, the δ cut of their fuzzy pvalue is
in which (H _{0b })_{ δ }=[θ _{1}(δ),θ _{2}(δ)] is the δ cut of the null hypothesis boundary and t is the observed test statistic.
Parchami et al. [15] and Fazlalipor et al. [7] combined the two abovementioned ideas of Filzmoser and Viertl [8] and Parchami et al. [14] by two different approaches which lead to the same solution for testing fuzzy hypotheses based on fuzzy data. For instance, when the form of the rejection region is T≥t _{ r }, the δ cut of their proposed fuzzy pvalue is
in which (H _{0b })_{ δ }=[θ _{1}(δ),θ _{2}(δ)] and \( \tilde {t}_{\delta }=\left [t_{1}(\delta),t_{2}(\delta) \right ] \) are δ cuts of null hypothesis boundary and test statistic, respectively.
Also, Geyer and Meeden [9] investigated the concepts of fuzzy pvalue and fuzzy confidence interval when both the hypotheses and data are crisp.
Unlike these studies, another efficient and simple pvaluebased method for testing fuzzy hypotheses is presented in this paper. The proposed method is on the basis of the probability measure of fuzzy event introduced by Zadeh [22]. Also, it must be mentioned that all results of this study coincide with the results of testing classical hypotheses, when the hypotheses reduce to two crisp sets on the parameter space.
This paper is organized as follows. Some preliminaries, motivations and basic definitions about testing fuzzy hypotheses are reviewed in Section “Fuzzy Hypotheses: Motivation and Basic Definitions”. In Section “Testing Fuzzy Hypotheses Based on a New pValueBased Approach”, we present a new pvaluebased approach for testing fuzzy hypotheses. Some illustrative examples are given in Section “Illustrative Examples”. An agricultural applied example is presented in Section “Application to Agricultural Studies”. Also, a conclusion is given in the final section.
Fuzzy Hypotheses: Motivation and Basic Definitions
Here, we are going to briefly review some basic concepts which are needed or developed through this paper.
Testing Statistical Hypotheses
Let X=(X _{1},…,X _{ n }) be a random sample with the observed value x=(x _{1},…,x _{ n }), where X _{ i } has the probability density function (p.d.f.) or the probability mass function (p.m.f.) f(x _{ i };θ), i=1,…,n, with the unknown parameter \(\theta \in \Theta \subseteq \mathbb {R}\). It will be assumed that the functional form of f(x;θ) is known. The problem of testing statistical hypotheses is to decide whether to accept (or reject) the null hypothesis “ H _{0}:θ∈Θ _{0}⊂Θ” against “\(H_{1}:\theta \in {\Theta _{0}^{c}}=\Theta \Theta _{0}\)”, based on the random sample X. Usually, statistical hypotheses are one of the following forms:

(i) H _{0} :θ=θ _{0} versus H _{1} :θ=θ _{1} (θ _{0}>θ _{1})

(ii) H _{0} :θ=θ _{0} versus H _{1} :θ=θ _{1} (θ _{0}<θ _{1})

(iii) H _{0} :θ≥θ _{0} versus H _{1} :θ<θ _{0}

(iv) H _{0} :θ≤θ _{0} versus H _{1} :θ>θ _{0}

(v) H _{0} :θ=θ _{0} versus H _{1} :θ≠θ _{0}
In which θ _{0} and θ _{1} are two known numbers and we named them the boundary of the null and alternative hypotheses, respectively. A test ϕ is said to be a test of (significance) level α∈ [0,1] if α _{ ϕ }≤α, where \(\phantom {\dot {i}\!} \alpha _{\phi } = \text {sup}_{\theta \in \Theta _{0}} P_{\theta } (\)rejection of H _{0}). Commonly, the statistical tests are based on a socalled test statistic T(X). In a nonrandomized test, the space of possible values of the test statistic t is decomposed into a rejection region and its complement, the acceptance region. Under some certain conditions, the rejection region usually takes one of the following forms:
where t _{ l }, t _{ r }, or t _{1} and t _{2} are certain quantiles of the distribution of T, so that α _{ ϕ }=α. In case (c), we may obtain t _{1} and t _{2} by the equal tails method, so that P _{ θ }(T≤t _{1})=P _{ θ }(T≥t _{2})=α/2. The hypothesis H _{0} is rejected if the value of t=t(x) falls into the rejection region. In usual tests, the critical regions of testing hypotheses (i) and (iii) are of form (1.a), the critical region of testing hypotheses (ii) and (iv) are of form (1.b) and the critical region of testing hypothesis (v) is of form (1.c). For more details, see [8, 11, 15].
Fuzzy Hypotheses: Motivation
The motivation of introducing fuzzy hypotheses can be briefly presented by considering the following example. Suppose that an experimenter is interested in evaluating the mean growth of a plant by measuring its diameter which is distributed by a normal distribution with unknown mean μ and known standard deviation σ. The traditional method is testing hypothesis “ H _{0}: μ=μ _{0}” against “ H _{1}: μ≠μ _{0}”, for a certain value μ _{0}, on the basis of a random sample X, where X _{ i }∼N(μ,σ ^{2}), i=1,…,n. But obviously, if the mean of the given sample is slightly different from μ _{0}, then the null hypothesis is acceptable, and a considerable difference from μ _{0} makes H _{0} unacceptable. Therefore, it is more appropriate and more reasonable to formulate the hypotheses H _{0} and H _{1} by fuzzy terms “near to μ _{0}” and “away from μ _{0}”, respectively. In other words, more realistic hypotheses are
which can be formulated by using Definition 1. Having faced by such real situations leads statisticians to reformulate some classical and crisp hypotheses by using fuzzy hypotheses. Considering the above discussion, the main problem studied in this work is to test fuzzy hypotheses
based on a random sample from a p.d.f. or p.m.f. f(x;θ), θ∈Θ (for more details, see Definition 1). This problem is called the problem of testing fuzzy hypotheses. In this paper, motivated by [22], we propose a new pvaluebased approach to such a problem. Concerning the common pvaluebased methods, the introduced method has some important advantages. The main advantage of the introduced method is that it is based on both null and alternative hypotheses, while the common methods are based on null hypothesis only.
Fuzzy Hypothesis and Its Boundary
Here, we review some basic concepts about fuzzy hypotheses from Taheri and Behboodian [18] and Parchami et al. [15], which are used in Section “Testing Fuzzy Hypotheses Based on a New pValueBased Approach”.
Definition 1.
Any hypothesis of form “\(\tilde {H}:\,\theta \) is H(θ)” is called a fuzzy hypothesis, where “ θ is H(θ)” implies that θ is in a fuzzy set of Θ, the parameter space, with membership function H(θ).
Note that the ordinary hypothesis “ H: θ=θ _{0}” is a fuzzy hypothesis with the membership function H(θ)=1 at θ=θ _{0}, and zero otherwise, i.e. the indicator function of the crisp set {θ _{0}}.
Definition 2.
(See also [1, 2]) (a) Fuzzy hypothesis \(\tilde {H}:\,\theta \) is H(θ) is called a fuzzy onesided hypothesis, if there exists θ _{1}∈Θ so that: (i) H(θ)=1 for θ≤θ _{1} (θ≥θ _{1}) and (ii) H is an decreasing (increasing) function of θ for θ>θ _{1} (θ<θ _{1}).
(b) Fuzzy hypothesis \(\tilde {H}:\,\theta \) is H(θ) is called a fuzzy twosided hypothesis, if there exists an interval [θ _{1},θ _{2}]⊂Θ so that: (i) H(θ)=1 for θ∈[θ _{1},θ _{2}] and (ii) H is an increasing function of θ for θ≤θ _{1} and is a decreasing function for θ≥θ _{2}.
Definition 3.
Theboundary of the fuzzy hypothesis \(\tilde {H}\) is a fuzzy subset of θ with membership function H _{ b } defined as follows:

(i) \(H_{b}(\theta)=\bigg \{ \begin {array}{lcc} H(\theta) &\ \ \ \text {for}&\ \ \ \theta \leq \theta _{1}, \\ \ \ 0 &\ \ \ \text {for}&\ \ \ \theta >\theta _{1} \end {array} \bigg \}\), if \(\tilde {H}\) is onesided and H is increasing,

(ii) \(H_{b}(\theta)=\bigg \{ \begin {array}{lcc} H(\theta) &\ \ \ \text {for}&\ \ \ \theta \geq \theta _{1}, \\ \ \ 0 &\ \ \ \text {for}&\ \ \ \theta <\theta _{1} \end {array} \bigg \}\), if \(\tilde {H}\) is onesided and H is decreasing,

(iii) H _{ b }(θ)=H(θ), if \(\tilde {H}\) is twosided.
Example 1.
Let X be an exponential random variable with unknown mean λ, i.e. \(f(x;\lambda)= \frac {1}{\lambda } e^{\frac {x}{\lambda }} \), x>0, λ>0. Suppose that
Then, the hypothesis “\(\tilde H:\,\lambda \) is H(λ)” is a fuzzy onesided hypothesis. So, by Definition 3,
is the boundary of the fuzzy hypothesis \(\tilde {H}\) (see Fig. 1).
Probability Measure Under a Fuzzy Hypothesis
Definition 4.
(Torabi and Behboodian [20]) Let the random variable X have p.d.f. or p.m.f. f(x;θ) and \(\tilde {H}:\,\theta \) is H(θ) is a fuzzy hypothesis where \(\int _{\theta } H(\theta)d\theta <\infty \). The weighted probability density function of X, under the fuzzy hypothesis \(\tilde {H}\), is defined by
where \(H^{*}(\theta)=\frac {H(\theta)}{\int _{\theta } H(\theta)d\theta }\) is the normalized membership function of H(θ). Replace integration by summation in discrete cases.
Remark 1.
(Torabi and Behboodian [20]) (a) The normalized membership function is not necessarily a membership function, i.e. it may be greater than 1 for some values of θ.(b) Note that \(f(x;\tilde {H})\) in Definition 4 is a p.d.f., since \(f(x;\tilde {H})\) is nonnegative and \(\int _{x}\,f(x;\tilde {H})dx=1\). (c) If H is the crisp hypothesis H:θ=θ _{0}, then \(f(x;\tilde H)=f(x;\theta _{0})\).
Example 2.
Let X be a normal random variable with unknown mean μ and variance 0.7. The weighted p.d.f. of X under fuzzy hypothesis “\(\tilde {H}:\mu \cong 4\)” is as follows:
where μ≅4 is defined by
The calculation process for the weighted p.d.f. of X under fuzzy hypothesis μ≅4 is drawn in Fig. 2 on the basis of Definition 4.
The major advantage of Definition 4 is that the weighted p.d.f. can integrate all possible p.d.f.s with different weights. The value of H ^{∗}(θ) can be understood as the weight of f(x;θ), and the weighted p.d.f. can let different possible f(x;θ)s play different roles in this integration (e.g. see Fig. 2 in Example 2).
Testing Fuzzy Hypotheses Based on a New pValueBased Approach
The pValue Approach
Similar to the usual kinds of hypotheses which are listed at the first of Section “Fuzzy Hypotheses: Motivation and Basic Definitions”, the fuzzy hypotheses can be usually modelled by one of the following forms:

(i) \(\ \ \bigg \{ \begin {array}{l} \tilde {H}_{0}:\theta \ \mathrm {is \ approximately} \ \theta _{0}, \\ \tilde {H}_{1}:\theta \ \mathrm {is \ approximately} \ \theta _{1}, \end {array} \ \ \mathrm {where \ Def}(H_{0})>\text {Def}(H_{1}),\)

(ii) \(\ \ \bigg \{ \begin {array}{l} \tilde {H}_{0}:\theta \ \mathrm {is \ approximately} \ \theta _{0}, \\ \tilde {H}_{1}:\theta \ \mathrm {is \ approximately} \ \theta _{1}, \end {array} \ \ \mathrm {where \ Def}(H_{0})<\text {Def}(H_{1}),\)

(iii) \(\ \ \bigg \{ \begin {array}{l} \tilde {H}_{0}:\theta \ \mathrm {is \ approximately \ bigger \ than} \ \theta _{0}, \\ \tilde {H}_{1}:\theta \ \mathrm {is \ approximately \ smaller \ than} \ \theta _{0}, \end {array}\)

(iv) \(\ \ \bigg \{ \begin {array}{l} \tilde {H}_{0}:\theta \ \mathrm {is \ approximately \ smaller \ than} \ \theta _{0}, \\ \tilde {H}_{1}:\theta \ \mathrm {is \ approximately \ bigger \ than} \ \theta _{0}, \end {array}\)

(v)\( \ \ \bigg \{ \begin {array}{l} \tilde {H}_{0}:\theta \ \mathrm {is \ near \ to} \ \theta _{0}, \\ \tilde {H}_{1}:\theta \ \mathrm {is \ away \ from} \ \theta _{0}, \end {array}\)
where θ _{0} and θ _{1} are two known numbers and Def(.) is a defuzzifier function. It is obvious that critical regions of testing fuzzy hypotheses are similar to the critical regions of testing precise hypotheses which are formulated by Relations (1). In other words, the critical regions of testing fuzzy hypotheses (i) and (iii) are of form (1.a), the critical regions of testing fuzzy hypotheses (ii) and (iv) are of form (1.b) and the critical region of testing fuzzy hypothesis (v) is of form (1.c). It must be noted that the critical regions of testing fuzzy hypotheses (i) and (ii) must be determined after defuzzification of the hypotheses, and it depends on the defuzzifier function.
Considering Definitions 1 and 3, one can assert that “\(\tilde {H}_{b}:\,\theta \ \text {is} \ H_{b}(\theta)\)” is a fuzzy hypothesis, and therefore we can generalize the classical pvalue for testing fuzzy hypothesis \(\tilde {H}_{0}\) against \(\tilde {H}_{1}\) as follows (see Subsection “Probability Measure Under a Fuzzy Hypothesis”, for more details about the probability measure under a fuzzy hypothesis).
Definition 5.
In testing fuzzy hypotheses problem, for any critical region of forms (1.a), (1.b) and (1.c), the pvalue is respectively defined as
and
where \(H^{*}_{0\,b}(\theta)=\frac {H_{0\,b}(\theta)}{\int _{\theta } H_{0\,b}(\theta)d\theta }\) is the normalized membership function of the boundary in the fuzzy null hypothesis, t is the observed value of test statistic (T) and \(m_{H_{0\,b}}\) is the median of the weighted distribution of T(X) under the boundary of the fuzzy null hypothesis \(\tilde {H}_{0\,b}\). Replacement of integration by summation is needed in discrete case.
Remark 2.
In contrast with previous pvalue methods in fuzzy environments (reviewed in Section “Introduction”), the proposed pvalue in this study is a real number on unit interval which is formulated according to the probability measure under fuzzy hypothesis.
Remark 3.
When the hypotheses are crisp rather than fuzzy, the membership function of the fuzzy boundary is reduced to the indicator function of a single point, i.e. the indicator function of the boundary θ _{0}. Then, the introduced pvalue for cases (a), (b) and (c) in Definition 5 are reduced to classical p values
and
where θ _{0} is the boundary of the null hypothesis and \(m_{\theta _{0}}\) is the median of T under θ _{0}, see [8] and page 381 of [11].
Decision Rule
In testing fuzzy hypothesis \( \tilde {H}_{0} \) against \( \tilde {H}_{1} \), suppose that p _{01} is the pvalue in testing \( \tilde {H}_{0} \) against \( \tilde {H}_{1} \) and p _{10} is the pvalue in testing \( \tilde {H}_{1} \) versus \( \tilde {H}_{0} \). Now we are going to extend the proposed method of Emadi and Arghami [5] for testing fuzzy hypotheses. It must be mentioned that the proposed decision rule omit several weaknesses of the classical pvaluebased tests which are point out in the next subsection.
Decision rule: Accept \( \tilde {H}_{1} \) with confidence factor \(\frac {p_{10} }{ p_{01} + p_{10} }\) if p _{01}<p _{10}; otherwise, accept \( \tilde {H}_{0} \) with confidence factor \(\frac {p_{01} }{ p_{01} + p_{10} }\). Therefore in this method, the “confidence factor into the given decision” can be introduced by
in which I(.) is the indicator function.
Advantages of the Proposed Method
Some advantages of the proposed decision rule with respect to the decision rule of the classical pvaluebased tests (i.e. reject null hypothesis at significance level α iff α>p _{01}) are presented as follows:

1.
The proposed decision rule is a function of both fuzzy hypotheses \( \tilde {H}_{0} \) and \( \tilde {H}_{1} \), while the current fuzzy pvalue methods are based on null fuzzy hypothesis (e.g. see Remark 7 in [14]).

2.
The proposed decision rule is symmetric with respect to the hypotheses. In other words, the acceptance (rejection) \( \tilde {H}_{0} \) versus \( \tilde {H}_{1} \) in this method is equivalent to the rejection (acceptance) \( \tilde {H}_{1} \) versus \( \tilde {H}_{0} \), while the previous pvaluebased methods in fuzzy environments do not have such reasonable property (see [16] for investigation on misleading statistical evidence by the current pvalue methods). Also, there exist such a symmetry in the introduced confidence factor, since \( \text {CF}(\tilde {H}_{0})=1\text {CF}(\tilde {H}_{1}) \).

3.
When \( \tilde {H}_{1} \longrightarrow \tilde {H}_{0} \), then p _{10}→p _{01} and therefore, \( \text {CF} \longrightarrow \frac {1}{2} \) which indicates a similar supporting data from both hypotheses. It must be mentioned that not only the usual pvalue methods for testing crisp hypotheses do not have this property but also the fuzzy pvaluebased methods for fuzzy environments do not have such property, e.g. see [8, 17].

4.
The previous fuzzy pvaluebased methods may not lead the user to a clear decision in twosided tests, when the fuzziness of the data or/and the fuzziness of the null hypothesis is/are high (for more details, see [7, 8, 14, 15]). This problem is solved in the proposed approach by omitting nodecision area in Formula (4).
Illustrative Examples
Example 3.
Let x=2.25 be an observation from N(μ,1) distribution. We wish to test
where \(\tilde {H}_{0}\) and \(\tilde {H}_{1}\) have membership functions
and H _{1}(μ)=1−H _{0}(μ) (see Fig. 3). Considering Definition 3, the membership function of the boundary of fuzzy null hypothesis is
The fuzzy hypotheses in this example can be modelled by form (iv) and so the rejection region is of form (1.b). Therefore, considering Relation (3), one can compute pvalue based on the weighted p.d.f. of X under \(\tilde {H}_{0\,b}\) as follows:
which is equivalent to the area of dark grey surface in Fig. 3. To decide on the basis of the proposed decision rule, we need to calculate the pvalue of testing \(\tilde {H}_{1}\) versus \(\tilde {H}_{0}\). Hence, one can similarly compute p _{10} as follows, which is equivalent to the area of light grey surface in Fig. 3
Therefore, p _{01}<p _{10}, and so we accept \(\tilde {H}_{1}\) against \(\tilde {H}_{0}\) with confidence factor \(\text {CF}=\frac {0.572}{0.156 + 0.572}=0.786\). Note that on the basis of the classical pvalue method, one accepts \(\tilde {H}_{0}\) against \(\tilde {H}_{1}\) at any significance level α<p _{01}=0.156. Although in this example, the result of the proposed method is in conflict with the result of the classical significance tests (e.g. at level 0.05), but we assert that the proposed method is much better according to the comparison of two grey surfaces in Fig. 3.
Example 4.
Let x=1.75 be an observation from N(μ,1) distribution. We wish to test
where \(\tilde {H}_{0}\) and \(\tilde {H}_{1}\) have membership functions (see the first graph in Fig. 4)
and
Considering Definition 3, the membership function of the boundary of fuzzy null hypothesis is equal to the membership function of the fuzzy null hypothesis. Also, the above fuzzy hypotheses can be modelled by form (ii), and so the rejection region for testing \(\tilde {H}_{0}\) versus \(\tilde {H}_{1}\) is of form (1.a). Therefore, considering Relation (2), one can compute pvalue based on the weighted p.d.f. of X under \(\tilde {H}_{0\,b}\) as follows:
To decide on the basis of the proposed decision rule, we need to calculate the pvalue of testing \(\tilde {H}_{1}\) versus \(\tilde {H}_{0}\). Hence, one can similarly compute \(p_{10}=P_{\tilde {H}_{1\,b}} (X\geq 1.75)=0.244 \). Therefore, p _{01}<p _{10}, and so we accept \(\tilde {H}_{1}\) against \(\tilde {H}_{0}\) with confidence factor \(\text {CF}=\frac {0.244}{0.019+0.244}=0.927\) (see the result of test 1 in Table 1).
To compare the results of several testing fuzzy hypotheses based on the proposed approach, five different tests are considered in this example by changing the fuzzy hypotheses (see Fig. 4). The membership functions of fuzzy hypotheses and the results of tests are presented in Table 1. Comparing the result of test 1 with the result of test 2 shows the sensitivity of the proposed approach to the location of the alternative fuzzy hypothesis (compare the first graph with the second one in Fig. 4). Also, comparing the result of test 1 with the result of test 3 shows the sensitivity of the proposed approach to the fuzziness of \( \tilde {H}_{1} \). Instead of the current fuzzy pvalue methods, the results of tests 1–5 show that the proposed decision rule in this paper is a function of both fuzzy hypotheses \( \tilde {H}_{0} \) and \( \tilde {H}_{1} \) (see the first advantage from Subsection “Advantages of the Proposed Method”).
Regarding to the used defuzzifier function \(\text {Def}(H)=\frac {\int _{\theta } \theta H(\theta) d\theta }{\int _{\theta } H(\theta) d\theta }\) in this example, the form of critical region is (1.b) for calculating p _{01} in test 5 (since Def(H _{0})<Def(H _{1})), while in tests 1–4, the form of critical region is of form (1.a).
Example 5.
The lifetime X of lamps (in terms of hour) produced by a factory is normally distributed with unknown mean μ and standard deviation σ=120. In a random sample of size n=36 lamps, we observe \( \bar x=1327\) h. We wish to test
where their membership functions are (see Fig. 5)
and
Considering Definitions 3 and 4, we have H _{ j b }(μ)=H _{ j }(μ) and \( H_{j\,b}^{*}(\mu)=\frac {H_{j\,b}(\mu)}{100}\), for j=0,1. In this example, fuzzy hypotheses can be modelled by form (ii) and the rejection region for testing \(\tilde {H}_{0}\) versus \(\tilde {H}_{1}\) is of form (1.b). Therefore, considering Relation (3), one can compute pvalue based on the weighted p.d.f. of X under \(\tilde {H}_{0\,b}\) as follows:
Similarly, \( p_{10}=P_{\tilde {H}_{1\,b}} (\bar {X}\leq 1327) = \int _{\mu }H^{*}_{1\,b}(\mu) \ P_{\mu }(\bar {X}\leq 1327) \ d\mu = 2.95\times 10^{7} \). Therefore, \(\tilde {H}_{0}\) is strongly accepted against \(\tilde {H}_{1}\) with confidence factor \(\text {CF}=\frac {0.285}{0.285+2.95\times 10^{7}}=0.999\).
Example 6.
The manager of a factory has reinstalled a new system to upgrade the security of his personnel. We can suppose that the number of monthly accidents has a Poisson distribution with unknown mean λ. A study shows that 27 accidents have occurred during the past year. Having installed the new system, the manager wants to test if the average of the monthly accidents is approximately bigger than 3. That is, to test
where their membership functions are
and H _{1}(λ)=1−H _{0}(λ) (see Fig. 6). Considering Definitions 3 and 4, \(H_{j\,b}^{*}(\lambda)= 4H_{j\,b}(\lambda) =4H_{j}(\lambda) I(2.75<\lambda \leq 3.25)\), where j=0,1. Fuzzy hypotheses are modelled by (iii) in this example, and the rejection region for testing \(\tilde {H}_{0}\) versus \(\tilde {H}_{1}\) is of form (1.a). By assumption, we have \( T(\textbf {X})=\sum _{i=1}^{12} X_{i} \sim \) Poisson(12 λ) while X=(X _{1},…,X _{12}), and therefore one can compute p _{01} and p _{10} by Relations (2) and (3), respectively, as follows:
Therefore, p _{01}<p _{10}, and \(\tilde {H}_{1}\) is accepted against \(\tilde {H}_{0}\) with confidence factor \(\text {CF}=\frac {0.895}{0.059+0.895}=0.938\).
Application to Agricultural Studies
This applied example was conducted on an agriculturally polluted soil with CdNO_{3} salt in a laboratory at Tehran University, Iran [10]. Suppose that we are going to have an investigation on the amount of cadmium (Cd) absorption in a plant from a polluted soil with CdNO_{3} salt. The unknown parameter is the amount of Cd absorption in a plant (in terms of mg.kg ^{−1} dry matter) from soil which we denoted it with μ. The optimum range of Cd absorbed in a plant has been proposed by Pais and Benton [12] as [0.05, 0.2], and also its maximum has been specified with 3 mg.kg ^{−1} dry matter. The experimenter wants to investigate on the following question: Whether the mean of Cd uptake coincides with the proposed suitable amounts by Pais and Benton or not?
In this applied example, one cannot represent the whole above presented information by Pais and Benton with a classical (precise) set. But, using fuzzy set theory, one can show the optimum range and the maximum amount of Cd uptakes in a plant by the following fuzzy set, in which the membership is considered to be one on the interval [0, 0.05], since the lower absorption of cadmium is better for any plant (Fig. 7)
Now, the experimenter can test fuzzy hypotheses \(\tilde {H}_{0}:\,\mu \) is H _{0}(μ), against \(\tilde {H}_{1}:\,\mu \) is H _{1}(μ) without facing any contradiction in the result, where the membership functions of \(\tilde {H}_{0}(\mu)\) and \(\tilde {H}_{1}(\mu)=1\tilde {H}_{0}(\mu)\) are shown in Fig. 7. This is an advantage of considering fuzzy hypotheses rather than crisp hypotheses in some practical problems.
In order to test fuzzy hypothesis \(\tilde {H}_{0}\) against \(\tilde {H}_{1}\), the experimenter has recorded the following data for the amount of Cd absorption via below radish parts from a random sample of size n=25 pots: 1.33, 1.42, 1.56, 1.85, 1.89, 2.96, 2.97, 1.60, 2.02, 1.78, 1.98, 1.86, 1.63, 1.56, 2.12, 1.35, 1.52, 1.32, 2.06, 1.38, 1.09, 2.50, 1.61, 1.46 and 2.18; see [13].
The sample mean is \(\bar {x} = 1.80\) mg.kg ^{−1} dry matter and the sample standard deviation is s=0.479 mg.kg ^{−1} dry matter. In this study, we assume that X _{ i }∼N(μ,s ^{2}), for i=1,…,25, in which the unknown variance parameter can be estimated by a maximum likelihood estimator \( s^{2}= \frac {1}{n} \sum _{i=1}^{n} (x_{i} \bar {x})^{2} \). Note that the normal distribution assumption for random variable X _{ i } comes from the essence of random variable X _{ i }, which is rooted from nature. For instance, one can accept that the weight of seeds picked from a particular plant type, the absorption amount of heavy metals through the roots of a plant in a special greenhouse experiment, or the growth rate of plants in a specific time period, are all normal random variables with suitable means and variances.
Considering Definitions 3 and 4, \(H_{j\,b}^{*}(\mu)= \frac {H_{j\,b}(\mu)}{1.4} =\frac {H_{j}(\mu)}{1.4} I(0.2<\lambda \leq 3)\), where j=0,1. Also, the form of fuzzy hypothesis \(\tilde {H}_{0}\) against \(\tilde {H}_{1}\) is (iv), hence the form of critical region is (1.b) and one can compute p _{01} by Relation (3) as follows:
Similarly, the form of fuzzy hypothesis \(\tilde {H}_{1}\) against \(\tilde {H}_{0}\) is (iii), hence the form of critical region is (1.a). So, one can compute p _{01} by Relation (2) as follows:
Therefore, p _{01}<p _{10}, and so \(\tilde {H}_{1}\) is accepted against \(\tilde {H}_{0}\) with confidence factor \(\text {CF}=\frac {0.328}{0.185+0.328}=0.639\). In other words, considering the confidence factor 0.639, one can assert that the mean absorption Cd in the lower radish parts does not coincides with the proposed amounts by Pais and Benton [12] and so it is not suitable.
Note that if the experimenter decides to solve this problem by classical pvalue method, first he/she must formulate the problem by one of the following hypotheses:
Test 1: H _{0}:μ≥0.2 against H _{1}:μ<0.2 and
Test 2: H _{0}:μ≥3 against H _{1}:μ<3,
while the results of tests 1 and 2 are in conflict with each other, for more details, see Tables 3–5 of [13]. It must be noted that the presented contradiction in the result of tests 1 and 2 comes from the difference between the null hypotheses in the two; in other words, it comes from very vague proposed information by Pais and Benton [12].
Conclusions
In this paper, a new pvaluebased approach was presented for testing statistical hypotheses when the hypotheses are fuzzy rather than crisp. In contrast with the commonly pvaluebased approach for testing fuzzy hypotheses, the decision rule in this approach is based on two pvalues: (1) the pvalue of testing fuzzy null hypothesis against fuzzy alternative hypothesis and (2) the pvalue of testing fuzzy alternative hypothesis against fuzzy null hypothesis. On the basis of this idea, therefore, the introduced method has several advantages over the common methods. The main advantage is that the proposed method is based on both the null and alternative hypotheses. Several numerical examples and also an agricultural example were provided to illustrate the performance of the method. The study of testing fuzzy hypotheses in the framework of uncertainty theory is a potential topic for future work. Also, the study of testing fuzzy hypotheses using the introduced pvalue and based on the paradigm of evidential statistics [16] is another potential topic for more research.
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Parchami, A., Taheri, S.M., Gildeh, B.S. et al. A Simple but Efficient Approach for Testing Fuzzy Hypotheses. J. Uncertain. Anal. Appl. 4, 2 (2016). https://doi.org/10.1186/s4046701500428
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DOI: https://doi.org/10.1186/s4046701500428
Keywords
 Fuzzy statistics
 Fuzzy hypothesis
 Testing hypothesis
 pvalue