Department of Social and Applied Science, College of Industrial Technology, King Mongkut's University of Technology North Bangkok, Pracharat 1 Road, Bangkok 10800, Thailand
2.
Department of Mathematics and Computer Science, Faculty of Science, Chulalongkorn University, 254 Phayathai Road, Bangkok 10330, Thailand
Received:
10 March 2024
Revised:
13 May 2024
Accepted:
29 May 2024
Published:
06 June 2024
This research explored the number of returns to the origin within the framework of a symmetric simple random walk. Our primary objective was to approximate the distribution of return events to the origin by utilizing the half-normal distribution, which is chosen for its appropriateness as a limit distribution for nonnegative values. Employing the Stein's method in conjunction with concentration inequalities, we derived an exponential non-uniform bound for the approximation error. This bound signifies a significant advancement in contrast to existing bounds, encompassing both the uniform bounds proposed by Döbler [1] and polynomial non-uniform bounds presented by Sama-ae, Chaidee, and Neammanee [2], and Siripraparat and Neammanee [3].
Citation: Tatpon Siripraparat, Suporn Jongpreechaharn. The exponential non-uniform bound on the half-normal approximation for the number of returns to the origin[J]. AIMS Mathematics, 2024, 9(7): 19031-19048. doi: 10.3934/math.2024926
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Abstract
This research explored the number of returns to the origin within the framework of a symmetric simple random walk. Our primary objective was to approximate the distribution of return events to the origin by utilizing the half-normal distribution, which is chosen for its appropriateness as a limit distribution for nonnegative values. Employing the Stein's method in conjunction with concentration inequalities, we derived an exponential non-uniform bound for the approximation error. This bound signifies a significant advancement in contrast to existing bounds, encompassing both the uniform bounds proposed by Döbler [1] and polynomial non-uniform bounds presented by Sama-ae, Chaidee, and Neammanee [2], and Siripraparat and Neammanee [3].
1.
Introduction
A symmetric simple random walk is a discrete-time stochastic process applicable in various fields, including physics, finance, biology, and probability theory. It is used to represent the movement of a particle involving randomness. Let X1,X2,…,Xn be independent, identically distributed, random variables with
P(Xi=1)=P(Xi=−1)=12,i=1,2,…,n.
The symmetric simple random walk is a process (Sn)n≥0 defined by
S0=0 and Sn=n∑i=1Xi for n≥1.
Here, Sn represents the position of the walk in the nth step.
For the sake of convenience, let us assume that n=2m for natural number m. We are interested in the number of returns to the origin, which is defined by
From the point probability formula (1.1), we are able to compute the probability distribution of the statistic Kn directly, particularly for cases where n is relatively small. For example, we have
P(K2≤1)=1∑i=0P(K2=i)=122(21)+12(11)=1.
In situations where n takes on large values, such as in this work where we assume that n≥4, the computation of the probability distribution becomes a time-consuming task and requires the utilization of a high-performance computing system. Consequently, this leads us to consider the approximation of the probability distribution of the statistic Kn. In [4], it is shown that
Kn=Kn√n
converges in distribution to a half-normal distribution denoted by H(z) as n→∞, where H(z) is defined by
H(z)={2Φ(z)−1,ifz≥0,0,ifz<0,
and Φ is a distribution function of a standard normal random variable. This implies that we can approximate the distribution of Kn using the half-normal distribution.
In the context of the approximation problem, it is imperative to establish a rigorous error bound stemming from the approximation. To this end, let ϵn(z) be the distance between the probability distribution of Kn and a half-normal distribution, i.e.,
ϵn(z)=|P(Kn≤z)−H(z)|,
and let
ϵn=supz≥0ϵn(z).
A bound on ϵn is termed a uniform bound, while a bound on ϵn(z) is referred to as a non-uniform bound. Döbler [1] showed in 2015 that when n is an even positive integer, the following uniform bound holds:
ϵn≤1√n(3.07521+1.5√n).
(1.2)
Subsequently, Sama-ae, Chaidee, and Neammanee [2] further refined the error bounds by presenting polynomial non-uniform bounds of degree 3, which exhibit greater precision compared to the uniform bound (1.2). Their result states that if z is a nonnegative real number and n is an even positive integer, then,
More recently, Siripraparat and Neammanee [3] improved the bound for the number of returns to the origin by introducing polynomial non-uniform bounds with an arbitrary degree k for any positive integer k. Presented below is their resultant finding. If z≥1, k∈N and n is an even positive integer such that n≥4, then,
where EKln≤⌊l2⌋−1∏i=0(2l−2i−1) for l=2,3,4,… and ⌊l2⌋ is the greatest integer less than or equal to l2.
Notice that the bound (1.4) decreases as k increases due to the term 1zk. However, the bound also incorporates the term EKk+1n, which increases with k. Consequently, in this study, we present a more precise bound in the form of an exponential non-uniform bound. The following represents our primary result.
Theorem 1.Let z be a nonnegative real number. For any even positive integer n such that n≥4, we have
The rest of this paper is structured as follows: Section 2 introduces Stein's method for half-normal approximation, while Section 3 presents the moment bounds for Kn and Kn. Section 4 is dedicated to proving a concentration inequality. Section 5 provides the proof of the main result. In Section 6, we present the application of Kn, and finally, Section 7 gives a conclusion.
2.
Stein's method on half-normal approximation
The primary technique employed to establish the main result, which provides a half-normal approximation, is Stein's method combined with concentration inequalities, as demonstrated by Döbler [1], Sama-ae, Chaidee, and Neammanee [2], and Siripraparat and Neammanee [3]. Stein [5] introduced a method to establish the bounds in the normal approximation for random variables, a technique known as Stein's method. This approach has been extended to various other distributions, including the Poisson distribution [6], binomial distribution [7], negative binomial distribution [8], beta distribution [9], variance-gamma distribution [10], Laplace distribution [11,12], and exponential distribution [13,14,15]. Moreover, the Stein's method can also be extended to work with random vectors as well [16].
We introduce Stein's method as applied to the half-normal distribution, which is employed to approximate the distribution of any random variable Döbler [1] utilized this approach and presented Stein's equation for the standard half-normal approximation, outlined as follows:
f′(x)−xf(x)=h(x)−H(z),
(2.1)
where f and h are continuous, piecewise, differentiable functions on [0,∞).
To derive an equation for the distribution function from Eq (2.1), we define a function hz:[0,∞)→R as follows for z≥0:
hz(x)={1, if 0≤x≤z,0, if x>z.
(2.2)
Consequently, for any random variable W, we obtain
E(f′z(W))−E(Wfz(W))=P(W≤z)−H(z),
(2.3)
where fz is the Stein solution of the differential Eq (2.1) with hz in (2.2) given by
fz(x)={√2πex22(1−Φ(z))(2Φ(x)−1), if x≤z,√2πex22(1−Φ(x))(2Φ(z)−1), if x>z,
(2.4)
for z≥0. Note that
f′z(x)={x√2πex22(1−Φ(z))(2Φ(x)−1)+2[1−Φ(z)], if x≤z,x√2πex22(1−Φ(x))(2Φ(z)−1)−2[Φ(z)−1], if x>z,
(2.5)
and
|f′z(x)|≤1for allx∈R,
(2.6)
(see Döbler [1,p. 177]). From (2.3), we can bound |E(f′z(W))−E(Wfz(W))| instead of |P(W≤z)−H(z)|. This technique is called Stein's method.
In order to prove our main result, we need the following properties of fz and f′z.
Proposition 1.Let x,z>0.
1)0<fz(x)<ex2−z22 for x≤z.
2)0<fz(x)<min(1,1z).
3)0≤f′z(x)≤ex2−z22+1.65e−z22 for x≤z.
Proof. 1) Let x≤z. By (2.4) and the fact that
1−Φ(x)≤e−x22√2πxforx>0([17,p.23]),
(2.7)
we obtain
fz(x)≤√2πex22e−z22√2πz(2Φ(1)−1)≤ex2−z22forz≥1.
Next, we consider z<1. By recalling (2.4) and (2.7), we get
Next, we utilize the facts (3.9) and (3.10) to eliminate the odd moment in the second term and the backward terms. This results in the remaining terms being even moments as follows:
Using a similar technique as in (3.12), we retain the odd moments while eliminating even moments, and thus, we establish
A2≤nk−32∑l=0(k−12l+1)EK2l+1n.
(3.13)
From (3.6) and (3.11)–(3.13), we complete the proof. □
Note that we can bound additional moments by employing Proposition 2, transforming Kn into Kn, and utilizing the initial moments presented in (3.2), (3.3), and taking into account the condition n≥4. Below are the fifth, sixth, and seventh moments for Kn:
From the demonstration above, it is evident that one can calculate all moments dependent on the forward moments. However, these calculations can be straightforward in contrast to complex. In the next proposition, we offer a bound for the moments of Kn that relies solely on the parameter k and does not depend on other moments. The technique used to derive this proposition is mathematical induction.
Proposition 3.Let n≥4. Then,
EKkn≤(k−1)!(k−4)(k−5),
for k∈N and k≥6.
Proof. Let k∈N with k≥6. The proof is divided into two cases.
Case 1:k is even and k≥6.
By (3.15), we see that
EK6n≤17.5625≤(k−1)!(k−4)(k−5)fork=6.
Assume that
EKkn≤(k−1)!(k−4)(k−5)
(3.17)
is true for k=6,8,10,…. By Proposition 2(1), and the fact that
To derive a bound for Bk+2, we apply the initial moments bound (3.3) while considering the conditions k≥6 and n≥4. This results in the bound (3.20) taking the form (k+1)!(k−2)(k−3) as follows:
Next, to obtain a bound for Ck+2, one can prove that, for a fixed l∈N such that l≥3, we have k(k−4)(k−5)(k−2l+1)!(2l)(2l−4)(2l−5)≤1 for k≥2l. From this fact, (3.21), and n≥4, we obtain that
From these two cases, we have completed the proof. □
4.
Concentration inequality
To prove our main theorem, we establish a concentration inequality for Kn. Notably, Döbler [1] was the first mathematician providing a uniform concentration inequality for Kn. His result is
P(z<Kn≤z+1√n)≤2√πnforz>0,
(4.1)
(see [1,p. 181]). The term "uniform concentration inequality" indicates that the obtained bound is independent of z. Subsequently, the concentration inequality (4.1) is extended to a non-uniform concentration inequality in terms of zk for k∈N, as detailed in [2,3]. In this section, we enhance the concentration inequality for Kn in terms of ez, presented in Proposition 4.
Then, we have f′(t)≥ez>0 for z−1√n<t<z+1√n, which implies that f is increasing.
We follow the argument of Sama-ae, Chaidee, and Neammanee ([2,pp. 784-785]) to obtain that
P(z<Kn≤z+1√n)≤1ez(H1+H2),
(4.2)
where
S|H1|=|2EKnf(Kn)|≤4√nE|KneKn+1√n|=4√ne1√nEKneKn,
(4.3)
and
|H2|=1√n|Ef(Kn)|≤2n|EeKn+1√n|=2ne1√nEeKn.
(4.4)
By Proposition 3, we have
∞∑k=6EKknk!=∞∑k=61k![(k−1)!(k−4)(k−5)]≤16,
and
∞∑k=6EKk+1nk!=∞∑k=61k![k!(k−3)(k−4)]≤12.
From these facts, (3.2), (3.3), (3.14), and (3.15), we obtain:
EeKn=∞∑k=0EKknk!≤2.9163,
(4.5)
and
EKneKn=∞∑k=0EKk+1nk!≤4.0442.
(4.6)
By (4.2)–(4.6), we conclude that for n≥4,
P(z<Kn≤z+1√n)≤31.4793ez√n.
□
5.
Proof of Theorem 1
In this section, we give an exponential non-uniform bound for Kn. From this point forward, we use f to denote fz, which is the unique solution of (2.4).
Proof of Theorem 1: By (1.2), we see that Theorem 1 is true for z=0. Now, we assume z>0 and n≥4. Döbler ([1,p. 179]) and Siripraparat and Neammanee ([3,p. 51]) showed that
Bounding |J1|: Applying the fundamental theorem of calculus and employing a truncation technique, we partition |J1| into two terms. By utilizing Proposition 1(3) in the first term and applying (2.6) in the second term, we can then obtain the following:
Bounding |J2|: By Markov's inequality, we obtain that
P(Kn≥3z4)≤EeKne3z4.
(5.3)
By employing a truncation technique together with the argument of |J1|, and utilizing Proposition 1(1), Proposition 1(2), (4.5), and (5.3), we establish
In this section, we provide an application of Theorem 1. Consider an option pricing following the binomial model (see [18,19] for more details) where the possible price of an option called "premium" is either increasing or decreasing. Let the initial premium be S0=0, which means that there is no change in the price. Let a random variable Xi be the change in the premium with distribution
P(Xi=1)=P(Xi=−1)=12,i=1,2,…,n.
Then, Sn=n∑i=1Xi represents the total change of the premium at period n. The premium is the same as at the initial state if Sn=0 for some period of time n. If we need to forecast the chance that the premium is the same as the initial state in a fixed period of time, we can approximate this by the half-normal distribution.
By applying Theorem 1, we obtain an error bound for the half-normal approximation. We present numerical results for (1.2)–(1.5) to emphasize the sharpness of our result compared to other bounds. The results are displayed in Table 1. It is worth noting that our exponential non-uniform bound rapidly decreases, especially when z is large.
Table 1.
Comparison of the constants C in uniform and non-uniform bounds in the form of C√n for large n.
In addition, when k=7 is fixed and the value of z varies from 30 to 200, we obtain the constants C in the form of C√n for each error bound, as shown in Figure 1. The graph is plotted on a semi-log scale on the vertical axis. We observe that the constant C for the bound (1.3) is approximately 10−5, and the bound (1.4) is approximately 10−9. However, our constant C for (1.5) ranges between 10−65 and 10−9, steadily decreasing as z increases. Indeed, the constant C for (1.5) provides the best error bound.
Figure 1.
Comparison of the constant C for error bounds (1.3), (1.4) when k=7, and (1.5) in the form of C√n.
By utilizing Stein's method, this study derived an exponential non-uniform bound for the difference between the number of returns to the origin and a half-normal distribution in a symmetric simple random walk. Comparing our exponential non-uniform bound with (1.2), (1.3), and (1.4), it is evident that our bound of this study is sharper as shown in Table 1. Consequently, Theorem 1 is more suitable for evaluating the accuracy of this approximation. We finally provided an example, an option pricing, that supported our research and illustrated the significance of the result. In future work, we will attempt to generalize these criteria to the scenario involving an asymmetric random walk.
Author contributions
All authors contributed equally to this work. They have read and approved the final version of the manuscript for publication.
Use of AI tools declaration
The authors declare they have not used Artificial Intelligence (AI) tools in the creation of this article.
Acknowledgments
The authors would like to thank the referees for all of the valuable comments and suggestions that helped to improve the quality of the manuscript.
Conflict of interest
All authors declare that they have no conflicts of interest.
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Tatpon Siripraparat, Suporn Jongpreechaharn. The exponential non-uniform bound on the half-normal approximation for the number of returns to the origin[J]. AIMS Mathematics, 2024, 9(7): 19031-19048. doi: 10.3934/math.2024926
Tatpon Siripraparat, Suporn Jongpreechaharn. The exponential non-uniform bound on the half-normal approximation for the number of returns to the origin[J]. AIMS Mathematics, 2024, 9(7): 19031-19048. doi: 10.3934/math.2024926