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A new generalized newsvendor model with random demand

Soham Ghosh, Mamta Sahare and Sujay Mukhoti111[email protected]
Operations Management and Quantitative Techniques Area
Indian Institute of Management, Indore
Rau-Pithampur Road, Rau, Indore, Madhya Pradesh, India- 453556
Abstract

Newsvendor problem is an extensively researched topic in inventory management. In this class of inventory problems, shortage and excess costs are considered to be proportional to the quantity lost. But, for critical goods or commodities, inventory decision is a typical example where, excess or shortage may lead to greater losses than merely the total cost. Such a problem has not been discussed much in the literature. Moreover, majority of the existing literature assumes the demand distribution to be completely known. In this paper, we propose a generalization of the newsvendor problem for critical goods or commodities with higher shortage or excess losses but of same degree. We also assume that, the parameters of the demand distribution are unknown. We also discuss different estimators of the optimal order quantity based on a random sample of demand. In particular, we provide different estimators based on (i) full sample and (ii) broken sample data (i.e with single order statistic). We also report comparison of the estimators using simulated bias and mean square error (MSE).

Keywords: Inventory Management, Newsvendor Problem, Power Loss Function, Random Demand, Optimal Order Quantity Estimation, Broken Sample.

1 Introduction

Newsvendor problem is one of the most extensively discussed problems in the inventory management literature due to its applicability in different fields (Silver et al., 1998). This inventory problem relies on offsetting the shortage and leftover cost in order to obtain optimal order quantity. In the standard newsvendor problem, each of the shortage and leftover costs are assumed to be proportional to the loss amount, i.e linear in the order quantity and demand. Also, the demand is assumed to be a random variable with known probability distributions. However, there may be situations where the loss is more severe than the usual linear one. Further in real life situations, the demand distribution is often unknown. In this paper, we generalize the classical newsvendor problem with non-linear losses and study the estimation of optimal order quantity subject to random demand with unknown parameters.

In classical newsvendor problem, we consider a newsvendor selling a perishable commodity procured from a single supplier. Further let the demand be a random variable. Newsvendor takes one time decision on how much quantity she should order from supplier. The newsvendor faces leftover cost if the demand is lower than the inventory, as a penalty for ordering too much. Similarly, shortage cost is faced if the demand is higher than the inventory, as a penalty for ordering too less. The shortage (leftover) cost is computed in terms of currency units as the product of per unit shortage cost and the loss amount, i.e difference between demand and inventory. Thus the loss is linear in difference between demand and inventory. To determine the optimal order quantity, the newsvendor has to minimize the total cost or maximize the total profit. This classical version of the newsvendor problem has been generalized, application wise, in many directions since its inception. Veinott Jr (1965) generalized the newsvendor model for multiple time periods. Extension of newsvendor problem for multiple products is being studied extensively in the literature (e.g., see Chernonog and Goldberg, 2018, and the references therein). We refer to a recent review by (Qin et al., 2011) for extensions of newsvendor problem that adds dimensions like marketing efforts, buyer’s risk appetite etc.

In many real life situations, the notion of loss may be higher than the quantity of lost units. For example, chemotherapy drugs are critical for administering it to a patient on the scheduled days. Shortage of the drug of that day would result in breaking the cycle of treatment. Hence the loss is not merely the quantity but more than that. Similarly, in the case of excess inventory, not only the excess amount of the drug but its disposal method also contributes to the notion of loss. This is due to the chance of vast environmental and microbial hazards that may be created through improper disposal, like creation anti-biotic resistant bacteria or super-bugs. Thus the losses due to excess and shortage could be thought of as non-linear.  Newsvendor problem with nonlinear losses, however, remains not much addressed until recently.

Chandra and Mukherjee (2005) have considered optimization of different risk alternatives to expected cost function, like cost volatility and Value-at-Risk, which results in non-linear objective functions. Parlar and Rempala (1992) considered the periodic review inventory problem and derived the solution for a quadratic loss function for both shortage and leftover. Gerchak and Wang (1997) proposed a newsvendor model using power type loss function for asset allocation. Their work assumes asymmetric losses with linear leftover but power type shortage loss with details only up to quadratic loss. In this paper we consider a generalization of the newsvendor problem in the line of Parlar and Rempala (1992) and Gerchak and Wang (1997), i.e. power type losses. In particular, we consider the shortage and excess losses as general power function of same degree. Determination of optimal order quantity from such a generalized newsvendor problem still remains unexplored to the best of our knowledge. Since the power of excess and shortage loss are same, we refer to this problem as symmetric generalized (SyGen) newsvendor problem.

An interesting observation that can be made from the newsvendor literature is that majority of related work considers a completely specified demand distribution, whereas in reality, it is seldom known. In such cases, the optimal order quantity needs to be estimated. Dvoretzky et al. (1952) first addressed the estimation problem in classical newsvendor setup using Wald’s decision theoretic approach. Scarf (1959); Hayes (1969); Fukuda (1960) considered estimation problems in inventory control using maximum likelihood estimation (MLE) under different parametric demand distributions. Conrad (1976) estimated the demand and hence the optimal order quantity for Poisson distribution. Nahmias (1994) estimated the optimal order quantity for Normal demand with unknown parameters and Agrawal and Smith (1996) estimated the order quantity for negative binomial demand. Sok (1980) in his master’s thesis, presented estimators of the optimal order quantity based on order statistics for parametric distributions including uniform and exponential. Rossi et al. (2014) has given bounds on the optimal order quantity using confidence interval for parametric demand distributions.

On the other hand, non-parametric estimation of optimal order quantity in a classical newsvendor problem is comparatively recent. For example, Bookbinder and Lordahl (1989) considered bootstrap estimator of the optimal order quantity and Pal (1996) discussed construction of asymptotic confidence interval of the cost using bootstrapping. Another important non-parametric data-driven approach is the sampling average approximation (SAA) (Kleywegt et al., 2001). In this method, the expected cost is replaced by the sample average of the corresponding objective function and then optimized. Levi et al. (2015) provides bounds of the relative bias of estimated optimal cost using SAA based on full sample data. Bertsimas and Thiele (2005) ranks the objective functions evaluated at each demand sample data and shows that the trimmed mean of the ordered objective functions leads to a convex problem ensuring robust and tractable solution.

In this paper we consider estimation of the optimal order quantity for parametric demand distributions under SyGen newsvendor set-up. In particular, we consider two specific demand distributions, viz. uniform and exponential. We present here the optimal order quantity and its estimators using (1) full data in a random sample and (2) order statistic from a full sample. We investigate the conditions for existence of the estimator of the optimal order quantity. Further, we do a simulation study to gauge the performance of different estimators in terms of bias and mean square error (MSE) for different shortage to excess cost ratio, degree of loss-importance and sample size.

Rest of this paper is organized as follows. Section 2. describes determination of optimal order quantities for uniform and exponential demand distribution using full sample and order statistics, along with the existence condition for the same, wherever required. In section 3, we investigate estimation of the optimal order quantity using full sample and order statistics. Results of simulation study is presented in section 4. Section 5 is the concluding section with discussion on the future problems.

2 SyGen: Symmetric generalized newsvendor problem

In a single period classical newvendor problem, the vendor has to order the inventory before observing the demand so that the excess and shortage costs are balanced out. Let us denote the demand by a positive random variable XX with cumulative distribution function (CDF) Fθ(x),θΘF_{\theta}(x),\;\theta\in\Theta and probability density function fθ(x)f_{\theta}(x). We further assume that the first moment of XX exists finitely. Suppose Q+Q\in\mathbb{R}^{+} is the inventory level at the beginning of period. Then, shortage loss is defined as (XQ)+(X-Q)^{+} and the excess loss is defined as (QX)+(Q-X)^{+}, where d+=max(d,0)d^{+}=max(d,0). Let CsC_{s} and CeC_{e} denote the per unit shortage and excess costs (constant) respectively and the corresponding costs are defined as Cs(XQ)+C_{s}(X-Q)^{+} and Ce(QX)+C_{e}(Q-X)^{+}. Thus the total cost can be written as a piece-wise linear function in the following manner:

χ={Cs(XQ) if X>QCe(QX) if XQ\displaystyle\chi=\left\{\begin{array}[]{cc}C_{s}(X-Q)&\mbox{ if }X>Q\\ C_{e}(Q-X)&\mbox{ if }X\leq Q\end{array}\right. (3)

The optimal order quantity (QQ^{*}) is obtained by minimizing the expected total cost, E[χ]E[\chi]. The analytical solution in this problem is given by Q=Fθ1(CsCe+Cs)Q^{*}=F_{\theta}^{-1}\left(\frac{C_{s}}{C_{e}+C_{s}}\right), that is the γth\gamma^{th} quantile of the demand distribution (γ=CsCs+Ce\gamma=\frac{C_{s}}{C_{s}+C_{e}}).

We propose the following extension the classical newsvendor problem replacing the piece-wise linear loss functions by piece-wise power losses of same degree. Thus, the generalized cost function is given by

χm={Cs(XQ)m if X>QCe(QX)m if XQ\displaystyle\chi_{m}=\left\{\begin{array}[]{cc}C_{s}(X-Q)^{m}&\mbox{ if }X>Q\\ C_{e}(Q-X)^{m}&\mbox{ if }X\leq Q\end{array}\right. (6)

The powers of losses on both sides of QQ on the support of XX being same we would refer to this problem as symmetric generalized (SyGen) newsvendor problem.

The expected total cost in SyGen newsvendort problem is given by,

E[χm]=0QCe(Qx)mfθ(x)𝑑x+QCs(xQ)mfθ(x)𝑑xE[\chi_{m}]={\int_{0}^{Q}C_{e}(Q-x)^{m}f_{\theta}(x)dx}+{\int_{Q}^{\infty}C_{s}(x-Q)^{m}f_{\theta}(x)dx}

In the subsequent sections, we show that the expected cost admits minimum for uniform and exponential distributions.

In order to do so, the first order condition (FOC) is given by

E[χm]Q=0QmCe(Qx)m1fθ(x)𝑑xQmCs(xQ)m1fθ(x)𝑑x=0\displaystyle\frac{\partial E[\chi_{m}]}{\partial Q}=\int_{0}^{Q}mC_{e}(Q-x)^{m-1}f_{\theta}(x)dx-\int_{Q}^{\infty}mC_{s}(x-Q)^{m-1}f_{\theta}(x)dx=0 (7)
\displaystyle\Rightarrow Ce0Q(Qx)m1fθ(x)𝑑x=CsQ(xQ)m1fθ(x)𝑑x\displaystyle C_{e}{\int_{0}^{Q}(Q-x)^{m-1}f_{\theta}(x)dx}=C_{s}{\int_{Q}^{\infty}(x-Q)^{m-1}f_{\theta}(x)dx}

It is difficult to provide further insight without having more information on fθ(x)f_{\theta}(x). In the following section, we assume two choices for the demand distribution - (i) Uniform and (ii) Exponential.

2.1 Optimal Order Quantity for SyGen Newsvendor with Uniform Demand

In this section, we consider the problem of determining optimal order quantity in SyGen newsvendor set up where the demand is assumed to be a UniformUniform random variable over the support (0,b)(0,b) . The pdf of demand distribution is given by,

fθ(x)={1bif 0<x<b0;otherwisef_{\theta}(x)=\left\{\begin{array}[]{cc}\frac{1}{b}&\;if\;0<x<b\\ 0;&\;otherwise\end{array}\right.

The minimum demand here is assumed to be zero without loss of generality, because any non-zero lower limit of the support of demand could be considered as a pre-order and hence can be pre-booked. Using Leibnitz rule and routine algebra, it can be shown that the optimal order quantity is given by Q=b1+αm{{Q^{*}=\frac{b}{1+\alpha_{m}}}}, where αm=(CeCs)1m\alpha_{m}=\left(\frac{C_{e}}{C_{s}}\right)^{\frac{1}{m}}. Corresponding optimal cost is Cs×bmm+1×Ce(Ce1/m+Cs1/m)m{{C_{s}\times\frac{b^{m}}{m+1}\times\frac{C_{e}}{\left(C_{e}^{1/m}+C_{s}^{1/m}\right)^{m}}}}. Notice that (Ce1/m+Cs1/m)m=Cs(1+α11/m)mCs\left(C_{e}^{1/m}+C_{s}^{1/m}\right)^{m}=C_{s}\left(1+\alpha_{1}^{1/m}\right)^{m}\geq C_{s}, and hence we get an upper bound of the optimal cost as Cebmm+1C_{e}\frac{b^{m}}{m+1}. Notice, large αm\alpha_{m} would imply small order quantity. In other words, if the cost of excess inventory is much larger than the shortage cost, then the newsvendor would order less quantity to avoid high penalty. Similarly, small αm\alpha_{m} would result in ordering closer to the maximum possible demand (bb) to avoid high shortage penalty. However, if the degree of loss (mm) is very high, then the optimum choice would be to order half the maximum possible demand, i.e. Qb2,asmQ^{*}\rightarrow\frac{b}{2},\;as\;m\rightarrow\infty.

2.2 Optimal Order Quantity for SyGen Newsvendor with Exponential Demand

Next we consider the demand to be exponentially distributed with mean λ{\lambda}. The pdf of exponential distribution is given by,

fλ(x)=1λexλ;x>0,λ>0f_{\lambda}(x)={\frac{1}{\lambda}}e^{-{\frac{x}{\lambda}}};\;x>0,\;\lambda>0

In this case the expected cost function becomes

E[χm]=0QCe(Qx)mfθ(x)𝑑x+QCs(xQ)mfθ(x)𝑑xE[\chi_{m}]={\int_{0}^{Q}C_{e}(Q-x)^{m}f_{\theta}(x)dx}+{\int_{Q}^{\infty}C_{s}(x-Q)^{m}f_{\theta}(x)dx} (8)

In the following theorem we derive the first order condition for optimal inventory in SyGen newsvendor problem with exponential demand.

Theorem 2.1.

Let the demand in a SyGen newsvendor problem be an exponential random variable XX with mean λ>0\lambda>0. Then the first order condition for minimizing the expected cost is given by

ψ(Q/λ)=eQλ[CsCe(1)m]\psi(Q/\lambda)=e^{-{\frac{Q}{\lambda}}}\left[{\frac{C_{s}}{C_{e}}}-(-1)^{m}\right] (9)

where ψ(Qλ)==j=0m1(1)j(Qλ)mj11(mj1)!\displaystyle\psi\left(\frac{Q}{\lambda}\right)==\sum_{j=0}^{m-1}(-1)^{j}\left(\frac{Q}{\lambda}\right)^{m-j-1}\frac{1}{(m-j-1)!}.

Proof.

Let us define, Im=0Q(Qx)m11λexλ𝑑xI_{m}={\int_{0}^{Q}(Q-x)^{m-1}{\frac{1}{\lambda}}e^{-{\frac{x}{\lambda}}}dx} and Jm=Q(xQ)m11λexλ𝑑xJ_{m}={\int_{Q}^{\infty}(x-Q)^{m-1}{\frac{1}{\lambda}}e^{-{\frac{x}{\lambda}}}dx}. Hence, the FOC in eq.(7) becomes

CeIm=CsJmC_{e}I_{m}=C_{s}J_{m} (10)

Assuming Qx=uQ-x=u, we get

Im\displaystyle I_{m} =\displaystyle= eQλλ0Qum1euλ𝑑u\displaystyle{\frac{e^{-{\frac{Q}{\lambda}}}}{\lambda}}{\int_{0}^{Q}u^{m-1}e^{\frac{u}{\lambda}}du}
=\displaystyle= eQλλ×[λeuλum1]0Qλ(m1)Im1, (integrating by parts)\displaystyle{\frac{e^{-{\frac{Q}{\lambda}}}}{\lambda}}\times\left[{\lambda}e^{\frac{u}{\lambda}}u^{m-1}\right]^{Q}_{0}-{\lambda}(m-1)I_{m-1},\hskip 4.0pt\mbox{ (integrating by parts)}
=\displaystyle= Qm1λ(m1)Qm2+λ2(m1)(m2)Im2\displaystyle Q^{m-1}-{\lambda}(m-1)Q^{m-2}+\lambda^{2}(m-1)(m-2)I_{m-2}
\displaystyle\ldots~{}\ldots~{}\ldots
=\displaystyle= j=0m1Qm1j(λ)j(m1)!(mj1)!+eQλλm1(1)m(m1)!\displaystyle{\sum_{j=0}^{m-1}}Q^{m-1-j}(-{\lambda})^{j}{\frac{(m-1)!}{(m-j-1)!}}+e^{-{\frac{Q}{\lambda}}}{\lambda}^{m-1}(-1)^{m}(m-1)!

Now letting, xQ=vx-Q=v in JmJ_{m}, we get

Jm=eQλλ0vm1evλ𝑑v=eQλΓ(m)λm1J_{m}={\frac{e^{-{\frac{Q}{\lambda}}}}{\lambda}}{\int_{0}^{\infty}v^{m-1}e^{-{\frac{v}{\lambda}}}dv}=e^{-{\frac{Q}{\lambda}}}{\Gamma}(m){\lambda}^{m-1}

Thus, from eq.(10), we get

CeIm=CsJm\displaystyle C_{e}I_{m}=C_{s}J_{m}
\displaystyle{\Rightarrow} j=0m1(1)j(Qλ)mj11(mj1)!=eQλ[CsCe(1)m]=γmeQλ\displaystyle{\sum_{j=0}^{m-1}}(-1)^{j}{\left(\frac{Q}{\lambda}\right)^{m-j-1}}{\frac{1}{{(m-j-1)!}}}=e^{-{\frac{Q}{\lambda}}}\left[{\frac{C_{s}}{C_{e}}}-(-1)^{m}\right]=\gamma_{m}e^{-{\frac{Q}{\lambda}}}

As a consequence of the above FOC condition for exponential demand, we need to inspect the existence of non-negative zeroes of eq.(9). We first provide lower and upper bound of ψ(Q/λ)\psi(Q/\lambda) in the following theorem.

Theorem 2.2.

For γm>0andm4\gamma_{m}>0\;and\;m\geq 4, the following inequality holds:

(1+γm)(u22u+1)+Sm4<ψ(u)<(1+γm)(u1)+Sm3-(1+\gamma_{m})\left(\frac{u^{2}}{2}-u+1\right)+S_{m-4}<\psi(u)<(1+\gamma_{m})(u-1)+S_{m-3}

where, ψ(u)=Sm1euγm\psi(u)=S_{m-1}-e^{-u}\gamma_{m} and Smk=j=0mk(1)jumj1(mj1)!\displaystyle S_{m-k}=\sum_{j=0}^{m-k}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}.

Proof.

Letting Qλ=u\frac{Q}{\lambda}=u, we obtain from eq. (9),

ψ(u)=j=0m1(1)jumj1(mj1)!euγm=0,where,γm=[CsCe(1)m]\psi(u)=\sum_{j=0}^{m-1}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}-e^{-u}\gamma_{m}=0,\;where,\;\gamma_{m}=\left[{\frac{C_{s}}{C_{e}}}-(-1)^{m}\right]

Since, eu>1u,e^{-u}>1-u,, for m3m\geq 3, we get

ψ(u)\displaystyle\psi(u) <\displaystyle< j=0m1(1)jumj1(mj1)!(1u)γm\displaystyle\sum_{j=0}^{m-1}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}-(1-u)\gamma_{m} (11)
=\displaystyle= ((1)m1γm)+((1)m2+γm)u+j=0m3(1)jumj1(mj1)!\displaystyle((-1)^{m-1}-\gamma_{m})+((-1)^{m-2}+\gamma_{m})u+\sum_{j=0}^{m-3}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}
=\displaystyle= ((1)m1γm)+((1)m2+γm)u+j=0m3(1)jumj1(mj1)!\displaystyle((-1)^{m-1}-\gamma_{m})+((-1)^{m-2}+\gamma_{m})u+\sum_{j=0}^{m-3}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}
=\displaystyle= ((1)m2+γm)(u1)+j=0m3(1)jumj1(mj1)!\displaystyle((-1)^{m-2}+\gamma_{m})(u-1)+\sum_{j=0}^{m-3}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}
\displaystyle\leq (1+γm)(u1)+Sm3,[ since, (1)m21]\displaystyle(1+\gamma_{m})(u-1)+S_{m-3},\;[\mbox{ since, }(-1)^{m-2}\leq 1]

On the other hand,using eu<1u+u22e^{-u}<1-u+\frac{u^{2}}{2}, it can be shown from eq. (9) that for m4m\geq 4,

ψ(u)\displaystyle\psi(u) \displaystyle\geq j=0m1(1)jumj1(mj1)!(1u+u22)γm\displaystyle\sum_{j=0}^{m-1}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}-\left(1-u+\frac{u^{2}}{2}\right)\gamma_{m} (12)
=\displaystyle= ((1)m1γm)+((1)m2+γm)u+((1)m3γm)u22\displaystyle((-1)^{m-1}-\gamma_{m})+((-1)^{m-2}+\gamma_{m})u+((-1)^{m-3}-\gamma_{m})\frac{u^{2}}{2}
+j=0m4(1)jumj1(mj1)!\displaystyle+\sum_{j=0}^{m-4}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}
=\displaystyle= ((1)m1γm)((1)m1γm)u+((1)m1γm)u22\displaystyle((-1)^{m-1}-\gamma_{m})-((-1)^{m-1}-\gamma_{m})u+((-1)^{m-1}-\gamma_{m})\frac{u^{2}}{2}
+j=0m4(1)jumj1(mj1)!\displaystyle+\sum_{j=0}^{m-4}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}
=\displaystyle= ((1)m1γm)(1u+u22)\displaystyle((-1)^{m-1}-\gamma_{m})(1-u+\frac{u^{2}}{2})
+j=0m4(1)jumj1(mj1)!\displaystyle+\sum_{j=0}^{m-4}(-1)^{j}\frac{u^{m-j-1}}{(m-j-1)!}
\displaystyle\geq ((1)γm)(1u+u22)+Sm4,[ since, (1)m11]\displaystyle((-1)-\gamma_{m})(1-u+\frac{u^{2}}{2})+S_{m-4},\;[\mbox{ since, }(-1)^{m-1}\geq-1]
=\displaystyle= (1+γm)(1u+u22)+Sm4\displaystyle-(1+\gamma_{m})(1-u+\frac{u^{2}}{2})+S_{m-4}

The following few remarks could be made immediately from the above theorem.

Remark.

For m=2km=2k, γm<0\gamma_{m}<0 implies Cs<CeC_{s}<C_{e}, in which case the direction of the above inequality will be altered. Further, for m=2k+1m=2k+1, γm\gamma_{m} is always positive as Cs,Ce>0C_{s},C_{e}>0.

Remark.

If m=2k+1m=2k+1, γm>0\gamma_{m}>0. In that case, we get from the lower boundary function in eq.(11),

gL(u)=u2k(2k)!u2k1(2k1)!++u44!u33!(1+γm)u22+u(1+γm)(1+γm)g_{L}(u)={\frac{u^{2k}}{(2k)!}}-{\frac{u^{2k-1}}{(2k-1)!}}+...+{\frac{u^{4}}{4!}}-{\frac{u^{3}}{3!}}-(1+{\gamma}_{m}){\frac{u^{2}}{2}}+u(1+{\gamma}_{m})-(1+{\gamma}_{m})

Therefore, by Descarte’s rule of sign, the maximum number of positive real roots is 2k12k-1 and hence there will exist at least one positive root.

Further, from the upper boundary function in eq.(12)

gU(u)=u2k(2k)!u2k1(2k1)!++u44!u33!+u22+u(1+γm)(1+γm)g_{U}(u)={\frac{u^{2k}}{(2k)!}}-{\frac{u^{2k-1}}{(2k-1)!}}+...+{\frac{u^{4}}{4!}}-{\frac{u^{3}}{3!}}+{\frac{u^{2}}{2}}+u(1+{\gamma}_{m})-(1+{\gamma}_{m})

Hence, by similar argument as in gL(u)g_{L}(u), at least one positive root of gU(u)g_{U}(u) will exist. Thus, both the boundary functions will have a positive root leading to the existence of positive root of ψ(u)\psi(u).

Remark.

If m(4)m\;(\geq 4) is even then, following the similar line of argument as in the previous remark, it can be shown that both gL(u)g_{L}(u) and gU(u)g_{U}(u) will have 2k12k-1 sign changes and hence at least one positive root.

Remark.

In the particular case of m=3m=3, it the boundary functions reduces to

gL(U)\displaystyle g_{L}(U) =\displaystyle= (2+CsCe)(u22u+1)\displaystyle(2+{\frac{C_{s}}{C_{e}}})({\frac{u^{2}}{2}}-u+1)
gU(u)\displaystyle\mbox{\& }g_{U}(u) =\displaystyle= (u1)(γm+1)+u22\displaystyle(u-1)({\gamma}_{m}+1)+{\frac{u^{2}}{2}}

Clearly, no real root of the lower boundary functions exist and the positive root of upper boundary function is given by (1+γm)+γm2+4γm+3-(1+\gamma_{m})+\sqrt{\gamma_{m}^{2}+4\gamma_{m}+3}.

Since eq. (9) is a transcendental equation in Q, numerical methods would be required to find zeros, which in turn would provide the optimal order quantity. However, the solution would be dependent on the shortage and excess cost ratio. In what follows, we describe the nature of solutions in different scenarios for α1=CsCe\alpha_{1}=\frac{C_{s}}{C_{e}}.

In case of equal shortage and excess costs (Cs=CeC_{s}=C_{e}), α1=1\alpha_{1}=1 and corresponding optimal order quantities (QQ^{*}) are given in the table below for different mm:

Table 1: Optimal Order Quantity for Cs=CeC_{s}=C_{e}.
m QQ^{*}
2 λ{\lambda}
3 1.3008λ1.3008{\lambda}
4 1.5961λ1.5961{\lambda}
10 3.33755λ3.33755{\lambda}
20 6.17753λ6.17753{\lambda}

On the other hand, if the shortage cost is much lower than the excess cost (α10\alpha_{1}\rightarrow 0), then the optimal order quantity (QQ^{*}) is very small (tends to 0). In case of 0<α1<10<\alpha_{1}<1, the optimum order quantity can be computed from the following equation:

j=0m1(1)j(Qλ)mj11(mj1)!=γmeQλ\sum_{j=0}^{m-1}(-1)^{j}\left(\frac{Q}{\lambda}\right)^{m-j-1}{\frac{1}{{(m-j-1)!}}}=\gamma_{m}e^{-{\frac{Q}{\lambda}}}

The two figures in appendix B, fig.1 provide the optimal order quantity as a multiple of the average demand (λ\lambda) obtained for α1(0,1)\alpha_{1}\in(0,1) and m=2,3,4,5,10,20,30,40,50,100m=2,3,4,5,10,20,30,40,50,100.

Notice that the differences between optimal order quantities corresponding to different α1\alpha_{1}s reduce with increasing mm. Here we may interpret mm as the degree of seriousness of the losses. Hence, the observation made above may also be restated in the following manner. As the degree of seriousness of the loss increases, the newsvendor becomes indifferent to both the losses. That is, beyond a risk level the newsvendor will not react much to the increase in any type of loss and order at a steady level, i.e become risk neutral.

In the following section we consider the parameters of the demand distributions discussed above, to be unknown and study the estimation of the optimal order quantity.

3 Estimation of the Optimal Order Quantity

In this section we consider the problem of estimating the optimal order quantity in SyGen newsvendor setup, based on a random sample of fixed size on demand, when the parameters of the two demand distributions discussed above are unknown.

3.1 Estimating Optimal Order Quantity for U(0,b)U(0,b) Demand

As in the previous section, we first consider the demand distribution to be uniform(0,b)uniform(0,b), where bb is unknown. We elaborate on the estimation of optimal order quantity in SyGen news vendor problem with available iid demand observations X1,X2XnX_{1},X_{2}\ldots X_{n}. Method of moment type estimator of the optimal order quantity could be constructed by plugging in the same for the unknown parameter bb. Thus,

Q^1=2x¯1+αm\hat{Q}_{1}=\frac{2\bar{x}}{1+\alpha_{m}} (13)

which is an unbiased estimator as well. The variance of Q^1\hat{Q}_{1} is given by V(Q^1)=b23n(1+αm)2V(\hat{Q}_{1})=\frac{b^{2}}{3n(1+\alpha_{m})^{2}}. In fact the uniformly minimum variance unbiased estimator (UMVUE) of the optimal order quantity can be obtained using the order statistics X(1)<X(2)<X(n)X_{(1)}<X_{(2)}\ldots<X_{(n)}. The UMVUE is given as follows:

Q^2=(n+1)X(n)n(1+αm)\hat{Q}_{2}=\frac{(n+1)X_{(n)}}{n(1+\alpha_{m})} (14)

The variance of the UMVUE is given by V(Q^2)=b2(1+αm)2n(n+2)V(\hat{Q}_{2})=\frac{b^{2}}{(1+\alpha_{m})^{2}n(n+2)}. Since X(n)X_{(n)} is the maximum likelihood estimator (MLE) of bb, the MLE of optimal order quantity can also be obtained as

Q^3=X(n)1+αm\hat{Q}_{3}=\frac{X_{(n)}}{1+\alpha_{m}} (15)

Note that Q^3\hat{Q}_{3} is biased with Bias(Q^3)=Q1n+1Bias(\hat{Q}_{3})=-Q^{*}\frac{1}{n+1} and mean square error (MSE)=Q22(n+1)(n+2)(MSE)=Q^{*2}\frac{2}{(n+1)(n+2)}. Comparing Q^1,Q^2\hat{Q}_{1},\;\hat{Q}_{2} and Q^3\hat{Q}_{3} in terms of their variances (MSE for Q^2\hat{Q}_{2}), it can be easily seen that the UMVUE provides the best estimator among the three. In particular, V(Q^2)<MSE(Q^3)<V(Q^1)b>0V(\hat{Q}_{2})<MSE(\hat{Q}_{3})<V(\hat{Q}_{1})\;\forall b>0.

3.2 Estimating Optimal Order Quantity for exp(λ\lambda) Demand

Let us now consider that the demand distribution to be exponential with unknown parameter λ>0\lambda>0. Let X1,X2,,XnX_{1},X_{2},\ldots,X_{n} be a random sample on demand. Thus the problem becomes estimation of optimal order quantity in this SyGen setup.

3.2.1 Estimating equation based on full sample

In order to provide a good estimator of the optimal order quantity based on the full sample, we replace the parametric functions of λ\lambda involved in the FOC eq. (9) by their suitable estimators. In particular, we focus on replacing (i) λ\lambda by its MLE, (ii) eQλ=F¯(Q)e^{-\frac{Q}{\lambda}}=\bar{F}(Q) by corresponding UMVUEs. Performances of the estimated optimal order quantities, QQ^{*}, is measured by the corresponding bias and MSE.

FIRST ESTIMATING EQUATION

Replacing λ{\lambda} in eq. (9) by its MLE X¯{\bar{X}}, the first estimating equation is obtained as follows:

j=0m1(1)j(QX¯)mj11(mj1)!=eQX¯γm\sum_{j=0}^{m-1}(-1)^{j}\left(\frac{Q}{\bar{X}}\right)^{m-j-1}{\frac{1}{{(m-j-1)!}}}=e^{-{\frac{Q}{\bar{X}}}}\gamma_{m} (16)

Let the solution of this estimating equation be denoted by Q1Q^{*}_{1}. Though Q1Q^{*}_{1} is a plug-in estimator, being a function of MLE, it still would be expected to perform well in terms of bias and MSE.

SECOND ESTIMATING EQUATION

The UMVUE of eQλ=F¯(Q)e^{-\frac{Q}{\lambda}}={\bar{F}}(Q) based on the SRS X1,X2,,XnX_{1},X_{2},...,X_{n} drawn from exp(λ)exp(\lambda) population is given by

TSRS=(1QW)+n1T_{SRS}=\left(1-{\frac{Q}{W}}\right)^{n-1}_{+}

where, W=i=1nXi=nX¯W={\sum_{i=1}^{n}}X_{i}=n{\bar{X}} and (d)+=max(d,0)(d)_{+}=max(d,0). First we replace eQλe^{-\frac{Q}{\lambda}} by TSRST_{SRS} in eq(9). Also, the UMVUE of λ\lambda, appearing in the coefficients of Qmj1,0jm1Q^{m-j-1},\;\forall 0\leq j\leq m-1, in eq(9), is given by X¯\bar{X}. Replacing the above two estimators in place of their corresponding estimands in FOC, the second estimating equation is obtained as

j=0m1(1)j(n1mj1)(QW)mj1=γm(1QW)+n1{\sum_{j=0}^{m-1}}(-1)^{j}\binom{n-1}{m-j-1}\left(\frac{Q}{W}\right)^{m-j-1}=\gamma_{m}\left(1-{\frac{Q}{W}}\right)^{n-1}_{+} (17)

Let the solution of the above estimating equation be denoted by Q^2\hat{Q}^{*}_{2}. This is also a plug-in estimator and we compare it with Q^1\hat{Q}_{1}^{*} in terms of bias and MSE, as provided in section 4.

3.2.2 Estimating equation based on order statistics

In case the full data is not available, it is more likely that the seller would be able to recall the worst day or the best day in terms of demand. The worst day demand would be represented by the smallest order statistic X(1)X_{(1)}, and the best day would be counted as the largest order statistic X(n)X_{(n)}. In general, if the observation on the ithi^{th} smallest demand out of a sample of size nn is available, viz. X(i)X_{(i)}, then we may consider the following two possible ways of estimating the optimal order quantity. One is to use estimating equation obtained by replacing λ\lambda with its unbiased estimator based on X(i)X_{(i)} in both sides of the eq. (9) (see Sengupta and Mukhuti, 2006, and references therein). Another estimating equation can be obtained by replacing λ\lambda by its unbiased estimator using X(i)X_{(i)} in the left hand side expression of eq. (9) and X(i)X_{(i)} based unbiased estimator of F¯(Q)\bar{F}(Q) in the right hand side of the same equation.

Sinha et al. (2006) provided an unbiased estimator of F¯(Q){\bar{F}}(Q) based on X(i+1)X_{(i+1)}, which is as follows:

hi+1(Zi+1)=j1=0j2=0ji=0dj1j2jiI(Zi+1>α1j1α2j2αijiQ)h_{i+1}(Z_{i+1})=\sum_{j_{1}=0}^{\infty}\sum_{j_{2}=0}^{\infty}\ldots\sum_{j_{i}=0}^{\infty}d_{j_{1}j_{2}\ldots j_{i}}I(Z_{i+1}>\alpha_{1}^{j_{1}}\alpha_{2}^{j_{2}}\ldots\alpha_{i}^{j_{i}}Q) (18)

where Zi=(ni+1)X(i)\displaystyle Z_{i}=(n-i+1)X_{(i)}, αk=ni+kni,k=1,2i\alpha_{k}=\frac{n-i+k}{n-i},\;k=1,2\ldots i, dj1j2ji=(1)1ji(ni)×\displaystyle d_{j_{1}j_{2}\ldots j_{i}}=\frac{(-1)^{\sum_{1}j_{i}}}{\binom{n}{i}}\times k=1i[(ik)αk]jk\displaystyle\prod_{k=1}^{i}\left[\frac{\binom{i}{k}}{\alpha_{k}}\right]^{j_{k}}, 1\sum_{1} extending over all even suffixes of jj. Further, an unbiased estimator of λ\lambda based on X(i)X_{(i)} is given by λ^=X(i)ai\hat{\lambda}=\frac{X_{(i)}}{a_{i}}, where ai=j=1i1nj+1a_{i}=\displaystyle\sum_{j=1}^{i}\frac{1}{n-j+1}. The first approach to estimate QQ would be through the estimating equation obtained by replacing λ\lambda with λ^\hat{\lambda} in eq. 9. Let the corresponding solution be denoted by Q^(1)\hat{Q}^{*}_{(1)}. The second approach for estimating QQ^{*} is to replace F¯(Q)\bar{F}(Q) by hi(Zi)h_{i}(Z_{i}) and λ\lambda by λ^\hat{\lambda} in eq. (9). We denote the corresponding estimator by Q^(2)\hat{Q}^{*}_{(2)}.

In the case of only the best day demand data being available, the largest order statistic X(n)X_{(n)} is observed. However, due to high complexity of computation we don’t investigate this case in details.

4 Simulation

In this section we present simulation studies for exponential demand in order to estimate the optimum order quantities from the estimating equations discussed above. Let us consider standard exponential demand distribution (exp(11)) and observe performances of the estimated optimal order quantities corresponding to different estimating equations over different values of mm and αm{\alpha_{m}}. In this simulation we draw samples of size nn, (=10,50,100,500,1000,5000,10000=10,50,100,500,1000,5000,10000). For a given sample size nn, the estimated optimal quantities are determined from each of the estimating equations described in the previous section. This procedure is repeated 10001000 times. We compute the bias in the estimated optimal order quantities by the average of (Q^Q\hat{Q}^{*}-Q^{*}) over these 10001000 repetitions, where QQ^{*} is true optimal order quantity and Q^\hat{Q}^{*} is its estimate. The tables below report bias and MSE of different estimators of the optimal order quantity.

Full sample bias and MSE of Q^1\hat{Q}_{1}^{*} are reported in tables 2a-2c, respectively and the same for Q^2\hat{Q}_{2}^{*} are given in tables 3a-3c. It can be observed from the figures that the bias and MSEs of these two estimators of QQ^{*} are comparable. Also, none of the two estimators uniformly outperforms the other in terms of absolute bias or MSE across the given degrees of importance of loss, mm , in either small or large sample cases.

Comparing the bias and MSE of the estimators of QQ^{*} based on 2nd2^{nd} order statistic (viz. Q^(1)\hat{Q}_{(1)}^{*} and Q^(2)\hat{Q}_{(2)}^{*}) given in tables Tab.4a-4c and Tab.5a-5c respectively, similar observations as in the full sample case, can be made. However, in this case, the margin in bias and/or MSE for certain (α1,m,n)(\alpha_{1},m,n) are much larger. For example, MSE of Q^(1)\hat{Q}_{(1)}^{*} is quite smaller than that of Q^(2)\hat{Q}_{(2)}^{*} for m=50m=50 over all the considered sample sizes, when α1=2\alpha_{1}=2, whereas similar margins could be observed favoring Q^(2)\hat{Q}_{(2)}^{*} in case of α1=1\alpha_{1}=1 and m=10m=10, for all sample sizes except 100 and 1000. Thus, neither of the two estimators outperform the other.

5 Conclusion

Contributions of our study in this paper are 2-fold. First we have proposed a generalization of the standard news vendor problem assuming random demand and higher degree of shortage and excess loss. In particular, we have developed a symmetric generalized news vendor cost structure using power losses of same degree for both of shortage and excess inventory. We have presented the method to determine the optimal order quantity. In particular, we have presented the analytical expression of the optimal order quantity for uniform demand. In case of exponential demand, determination of optimal order quantity requires finding zeroes of a transcendental equation. We have proven the existence of real roots of the equation, ensuring that there exists a realistic solution to the proposed general model. Our second contribution is to provide different estimators of the optimal order quantity. We have provided estimators of the optimal order quantity using (i) full sample and (ii) broken sample data on demand. Whereas, analytical form of the estimator and its properties are easy to verify for uniform demand distribution, it is difficult for exponential distribution. We have presented a simulation study to compare different estimators. In this paper, we have presented estimators based on full sample as well as broken sample like single order statistic. Finally, we have provided a simulation study to gauge the performance of the proposed estimators in terms of bias and MSE.

A natural extension of this work could be to consider asymmetric shortage and excess losses. However, asymmetric power type shortage and excess losses would result in different dimensions of shortage and excess costs making them incomparable. Unpublished manuscript by Baraiya and Mukhoti (2019) proposes an inventory model for such a case.

Acknowledgement

3rd3^{rd} author remains deeply indebted to Late Prof. S Sengupta and Prof. Bikas K Sinha for their intriguing discussions and guidance on broken sample estimation. Research of 1st1^{st} author is funded by Indian Institute of Management Indore. The authors acknowledge gratefully the valuable comments by the participants of the SMDTDS-2020 conference organized by IAPQR at Kolkata.

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Appendix A Tables

Table 2a: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^1\hat{Q}^{*}_{1} for Cs=2CeC_{s}=2C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.0052 -0.0070 -0.0010 0.0011 -0.0007 0.0004 -0.0006
0.0597 0.0113 0.0060 0.0012 0.0005 0.0001 0.0001
3 0.6206 0.5937 0.6070 0.6116 0.6076 0.6099 0.6079
0.6775 0.4074 0.3976 0.3800 0.3718 0.3726 0.3698
4 13.1606 12.9312 13.0446 13.0836 13.0495 13.0695 13.0523
194.3676 171.1996 172.2751 171.6106 170.4826 170.8554 170.3837
5 -0.0927 -0.1180 -0.1055 -0.1012 -0.1050 -0.1028 -0.1047
0.2664 0.0624 0.0369 0.0155 0.0134 0.0111 0.0112
10 3.0587 2.9607 3.0092 3.0258 3.0112 3.0198 3.0124
13.2180 9.4926 9.4406 9.2340 9.1028 9.1270 9.0786
20 -4.4660 -4.4904 -4.4784 -4.4742 -4.4778 -4.4757 -4.4776
20.1848 20.2090 20.0797 20.0235 20.0533 20.0325 20.0487
50 -10.9240 -10.9797 -10.9522 -10.9427 -10.9510 -10.9461 -10.9503
120.5828 120.7890 120.0743 119.7677 119.9350 119.8197 119.9100
Table 2b: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^1\hat{Q}^{*}_{1} for Cs=CeC_{s}=C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.0978 0.0805 0.0891 0.0920 0.0895 0.0910 0.0897
0.1299 0.0291 0.0200 0.0109 0.0091 0.0085 0.0082
3 1.8820 1.8318 1.8566 1.8651 1.8577 1.8621 1.8583
4.5529 3.5459 3.5480 3.4993 3.4603 3.4694 3.4543
4 -0.5893 -0.6052 -0.5973 -0.5946 -0.5970 -0.5956 -0.5968
0.4485 0.3853 0.3669 0.3556 0.3573 0.3549 0.3563
5 0.0128 -0.0172 -0.0024 0.0027 -0.0017 0.0009 -0.0014
0.3614 0.0683 0.0361 0.0074 0.0033 0.0007 0.0004
10 11.3833 11.1515 11.2661 11.3055 11.2711 11.2913 11.2739
151.2083 128.4259 129.0847 128.2545 127.2342 127.5375 127.1223
20 -4.3518 -4.3806 -4.3664 -4.3615 -4.3657 -4.3632 -4.3654
19.2711 19.2521 19.0983 19.0292 19.0627 19.0385 19.0570
50 -8.2308 -8.3314 -8.2817 -8.2646 -8.2795 -8.2708 -8.2783
71.8199 70.1792 68.9928 68.3861 68.5878 68.4136 68.5345
Table 2c: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^1\hat{Q}^{*}_{1} for Cs=0.5CeC_{s}=0.5C_{e}
mm n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.1296 0.1074 0.1184 0.1222 0.1189 0.1208 0.1191
0.2148 0.0488 0.0338 0.0189 0.0159 0.0150 0.0144
3 4.5171 4.4217 4.4689 4.4851 4.4709 4.4793 4.4721
24.0654 20.2408 20.3366 20.1907 20.0227 20.0712 20.0034
4 -0.5046 -0.5252 -0.5150 -0.5115 -0.5146 -0.5128 -0.5143
0.4257 0.3080 0.2823 0.2651 0.2664 0.2633 0.2647
5 1.2617 1.2088 1.2349 1.2439 1.2361 1.2407 1.2367
2.7166 1.6729 1.6374 1.5702 1.5381 1.5416 1.5306
10 -2.2265 -2.2468 -2.2367 -2.2333 -2.2363 -2.2345 -2.2361
5.1226 5.0790 5.0195 4.9909 5.0025 4.9934 5.0001
20 -4.2357 -4.2689 -4.2525 -4.2468 -4.2517 -4.2488 -4.2513
18.3848 18.3069 18.1277 18.0444 18.0814 18.0536 18.0743
50 0.1000 -0.1344 -0.0185 0.0213 -0.0135 0.0069 -0.0107
22.1078 4.1763 2.2061 0.4496 0.2016 0.0449 0.0223
Table 3a: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^2\hat{Q}^{*}_{2} for Ce=2CsC_{e}=2C_{s}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 -0.0040 -0.0062 0.0024 0.0000 -0.0003 -0.0001 -0.0002
0.0566 0.0110 0.0060 0.0012 0.0006 0.0001 0.0001
3 0.6517 0.6058 0.6197 0.6102 0.6091 0.6090 0.6087
0.7187 0.4211 0.4138 0.3785 0.3740 0.3715 0.3709
4 13.4388 13.1458 13.2482 13.1041 13.0796 13.0654 13.0613
201.9324 176.7958 177.6949 172.1608 171.2964 170.7480 170.6197
5 -0.0795 -0.1103 -0.0954 -0.1028 -0.1037 -0.1036 -0.1039
0.2606 0.0597 0.0352 0.0160 0.0134 0.0113 0.0111
10 3.1096 2.9906 3.0482 3.0195 3.0161 3.0164 3.0154
13.4791 9.6562 9.6832 9.1984 9.1368 9.1061 9.0969
20 -4.4347 -4.4792 -4.4667 -4.4754 -4.4765 -4.4765 -4.4768
19.9084 20.1073 19.9757 20.0342 20.0411 20.0399 20.0419
50 -10.9395 -10.9700 -10.9336 -10.9470 -10.9486 -10.9481 -10.9486
120.8739 120.5714 119.6690 119.8620 119.8843 119.8641 119.8738
Table 3b: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^2\hat{Q}^{*}_{2} for Cs=2CeC_{s}=2C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.1491 0.0942 0.1002 0.0918 0.0907 0.0904 0.0902
0.1502 0.0314 0.0223 0.0109 0.0095 0.0084 0.0083
3 1.9619 1.8564 1.8812 1.8628 1.8606 1.8604 1.8599
4.8798 3.6337 3.6416 3.4912 3.4723 3.4630 3.4602
4 -0.5811 -0.6003 -0.5910 -0.5956 -0.5962 -0.5962 -0.5963
0.4374 0.3791 0.3595 0.3569 0.3565 0.3556 0.3557
5 0.0309 -0.0070 0.0101 0.0009 -0.0002 -0.0002 -0.0004
0.3582 0.0668 0.0368 0.0076 0.0038 0.0007 0.0004
10 11.5039 11.2222 11.3586 11.2907 11.2825 11.2832 11.2810
153.6697 129.9282 131.2102 127.9323 127.5194 127.3534 127.2837
20 -4.3348 -4.3713 -4.3546 -4.3633 -4.3643 -4.3642 -4.3645
19.1194 19.1696 18.9964 19.0449 19.0506 19.0472 19.0494
50 -8.3287 -8.3343 -8.2585 -8.2744 -8.2763 -8.2746 -8.2754
73.1996 70.2044 68.6129 68.5503 68.5387 68.4776 68.4869
Table 3c: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^2\hat{Q}^{*}_{2} for Cs=2CeC_{s}=2C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.1288 0.1119 0.1261 0.1205 0.1198 0.1200 0.1198
0.2084 0.0489 0.0359 0.0187 0.0164 0.0148 0.0146
3 4.7220 4.5005 4.5335 4.4846 4.4784 4.4765 4.4753
26.0939 20.9409 20.9274 20.1881 20.0944 20.0462 20.0321
4 -0.4644 -0.5131 -0.5038 -0.5122 -0.5132 -0.5134 -0.5137
0.3920 0.2951 0.2713 0.2660 0.2652 0.2639 0.2640
5 1.2892 1.2249 1.2560 1.2405 1.2387 1.2388 1.2383
2.7712 1.7080 1.6916 1.5625 1.5460 1.5369 1.5347
10 -2.2054 -2.2386 -2.2276 -2.2344 -2.2352 -2.2352 -2.2354
5.0296 5.0418 4.9791 4.9959 4.9978 4.9965 4.9973
20 -4.2275 -4.2598 -4.2397 -4.2490 -4.2502 -4.2500 -4.2503
18.3061 18.2278 18.0200 18.0635 18.0684 18.0636 18.0658
50 0.0614 -0.1994 -0.0146 -0.0146 -0.0126 -0.0034 -0.0046
21.3335 4.0419 2.2135 0.4609 0.2292 0.0443 0.0239
Table 4a: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^(1)\hat{Q}^{*}_{(1)} for Cs=2CeC_{s}=2C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.0311 0.0057 0.0044 0.0118 0.0130 0.0042 0.0257
0.3344 0.2931 0.2813 0.3175 0.2928 0.3210 0.3657
3 0.6780 0.6219 0.6189 0.6353 0.6379 0.6185 0.6660
2.0924 1.8219 1.7604 1.9575 1.8396 1.9542 2.2309
4 13.6486 13.1712 13.1460 13.2854 13.3079 13.1422 13.5463
304.4965 277.3833 272.5336 289.0052 280.8245 286.5041 312.9112
5 -0.0388 -0.0915 -0.0943 -0.0789 -0.0765 -0.0947 -0.0501
1.4415 1.2740 1.2235 1.3767 1.2693 1.3950 1.5789
10 3.2672 3.0633 3.0525 3.1120 3.1216 3.0508 3.2235
32.2458 28.3435 27.5137 30.2142 28.6722 30.0715 34.0053
20 -4.4141 -4.4649 -4.4676 -4.4528 -4.4504 -4.4680 -4.4250
20.8213 21.1102 21.0868 21.0992 20.9786 21.2496 21.0440
50 -10.8054 -10.9214 -10.9275 -10.8936 -10.8882 -10.9285 -10.8303
123.7353 125.4102 125.2968 125.3128 124.6758 126.1481 124.9338
Table 4b: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^(1)\hat{Q}^{*}_{(1)} for Cs=CeC_{s}=C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.1346 0.0986 0.0967 0.1073 0.1089 0.0965 0.1269
0.6903 0.6005 0.5763 0.6512 0.6016 0.6563 0.7519
3 1.9886 1.8843 1.8788 1.9092 1.9141 1.8779 1.9663
9.6012 8.5136 8.2929 9.0191 8.6186 8.9619 10.0476
4 -0.5556 -0.5886 -0.5903 -0.5807 -0.5791 -0.5906 -0.5626
0.8739 0.8432 0.8253 0.8751 0.8314 0.8929 0.9354
5 0.0765 0.0142 0.0109 0.0291 0.0320 0.0104 0.0632
2.0236 1.7737 1.7021 1.9211 1.7715 1.9423 2.2128
10 11.8767 11.3942 11.3687 11.5096 11.5323 11.3648 11.7733
261.8440 235.9926 231.1351 247.4247 238.9786 245.4252 270.8390
20 -4.2906 -4.3505 -4.3536 -4.3362 -4.3333 -4.3541 -4.3034
20.2683 20.5605 20.5222 20.5714 20.4089 20.7477 20.5546
50 -8.0167 -8.2261 -8.2372 -8.1760 -8.1662 -8.2389 -8.0616
87.0193 87.6663 87.0425 88.5002 86.6497 89.7789 89.8955
Table 4c: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^(1)\hat{Q}^{*}_{(1)} for Cs=0.5CeC_{s}=0.5C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.1768 0.1306 0.1282 0.1417 0.1439 0.1278 0.1669
1.1370 0.9889 0.9491 1.0724 0.9909 1.0807 1.2383
3 4.7201 4.5216 4.5111 4.5691 4.5784 4.5095 4.6776
42.7250 38.4152 37.5964 40.3345 38.9017 40.0158 44.2617
4 -0.4607 -0.5036 -0.5059 -0.4933 -0.4913 -0.5062 -0.4699
1.1676 1.0934 1.0618 1.1526 1.0797 1.1759 1.2667
5 1.3742 1.2641 1.2583 1.2905 1.2956 1.2574 1.3506
8.1699 7.1191 6.8820 7.6434 7.1903 7.6275 8.7005
10 -2.1833 -2.2255 -2.2278 -2.2154 -2.2135 -2.2281 -2.1924
5.6909 5.7651 5.7423 5.7875 5.7101 5.8538 5.8179
20 -4.1650 -4.2341 -4.2378 -4.2176 -4.2143 -4.2383 -4.1798
19.8266 20.1071 20.0502 20.1477 19.9362 20.3501 20.1851
50 0.5986 0.1109 0.0852 0.2276 0.2505 0.0812 0.4941
123.7725 108.4855 104.1096 117.5048 108.3515 118.8006 135.3470
Table 5a: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^(2)\hat{Q}^{*}_{(2)} for Cs=2CeC_{s}=2C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 -0.0625 -0.1219 -0.0799 -0.1007 -0.1041 -0.1025 -0.1056
0.2761 0.2108 0.2245 0.2384 0.2546 0.2371 0.2576
3 0.5977 0.4855 0.5937 0.5472 0.5395 0.5451 0.5376
1.9156 1.4015 1.6598 1.6739 1.7599 1.6658 1.7779
4 13.2132 12.6096 13.6049 13.2154 13.1489 13.1931 13.1255
291.3362 251.0958 288.8477 284.1045 289.9123 282.9913 290.7649
5 -0.1042 -0.1701 -0.0614 -0.1039 -0.1112 -0.1064 -0.1138
1.4026 1.1268 1.2407 1.3157 1.4074 1.3100 1.4255
10 3.0143 2.7592 3.1798 3.0152 2.9871 3.0058 2.9772
29.9356 24.0600 28.6405 28.6393 29.8210 28.4890 30.0241
20 -4.5136 -4.5327 -4.4134 -4.4535 -4.4608 -4.4556 -4.4627
21.6035 21.5750 20.6595 21.0824 21.2326 21.0951 21.2678
50 -11.1292 -11.2668 -11.0399 -11.1287 -11.1439 -11.1338 -11.1492
129.9304 131.7310 127.2745 129.5401 130.2713 129.6265 130.4667
Table 5b: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^(2)\hat{Q}^{*}_{(2)} for Cs=CeC_{s}=C_{e}
m n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.1857 0.2157 0.3067 0.2795 0.2740 0.2783 0.2725
0.8032 0.7401 0.8810 0.9173 0.9725 0.9135 0.9837
3 2.0321 1.8945 2.1214 2.0326 2.0174 2.0275 2.0121
10.2007 8.3781 9.8960 9.8237 10.1555 9.7758 10.2103
4 -0.5965 -0.6378 -0.5697 -0.5963 -0.6009 -0.5979 -0.6025
0.9022 0.8377 0.8101 0.8679 0.9087 0.8672 0.9175
5 -0.2011 -0.2469 -0.1175 -0.1674 -0.1741 -0.1685 -0.1766
1.5988 1.3269 1.4608 1.5476 1.6572 1.5434 1.6790
10 11.2783 10.6747 11.6700 11.2805 11.2140 11.2581 11.1905
243.9466 206.0419 239.9422 236.7064 242.7717 235.6797 243.7150
20 -4.4437 -4.4980 -4.3694 -4.4175 -4.4258 -4.4206 -4.4287
21.3903 21.5558 20.5983 21.1017 21.2846 21.1207 21.3313
50 -8.4431 -8.6981 -8.2775 -8.4421 -8.4703 -8.4516 -8.4802
92.1351 92.1044 87.0470 90.8175 92.6434 90.8839 93.0735
Table 5c: Bias (in 1st1^{st} row) and MSE (in 2nd2^{nd} row) of Q^(2)\hat{Q}^{*}_{(2)} for Cs=0.5CeC_{s}=0.5C_{e}
mm n=n=10 n=n=50 n=n=100 n=n=500 n=n=1000 n=n=5000 n=n=10000
2 0.0783 -0.0096 0.0751 0.0353 0.0286 0.0322 0.0261
1.0075 0.7557 0.8501 0.8859 0.9455 0.8799 0.9566
3 4.6372 4.3821 4.8027 4.6381 4.6100 4.6286 4.6001
42.3529 35.6494 41.5951 41.0597 42.1501 40.8788 42.3211
4 -0.4795 -0.4729 -0.3671 -0.4008 -0.4066 -0.4019 -0.4084
1.2028 1.0670 1.0989 1.1834 1.2596 1.1810 1.2757
5 1.2377 1.1001 1.3270 1.2382 1.2230 1.2331 1.2177
7.6032 5.9993 7.1566 7.2254 7.5813 7.1856 7.6446
10 -2.1798 -2.2379 -2.1481 -2.1815 -2.1869 -2.1827 -2.1889
5.7243 5.7721 5.4737 5.6682 5.7558 5.6704 5.7768
20 -4.4662 -4.6036 -4.4881 -4.5374 -4.5444 -4.5388 -4.5471
21.8757 22.6154 21.7307 22.2611 22.4430 22.2681 22.4902
50 -0.1642 -0.7678 0.2275 -0.1620 -0.2285 -0.1843 -0.2519
116.7738 92.6822 103.8056 109.4833 117.0710 108.9685 118.5504

Appendix II Figures

Refer to caption
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Figure 1: Optimal Order Quantity (QQ^{*}) for different α1(0,1)\alpha_{1}\in(0,1) and mm.