• 호남수학학술지
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• 제31권3호
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• pp.369-380
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• 2009

Let $X,X_1,X_2,\;{\cdots}$ be identically distributed and negatively associated random variables with mean zeros and positive, finite variances. We prove that, if $E{\mid}X_1{\mid}^r$ < ${\infty}$, for 1 < p < 2 and r > $1+{\frac{p}{2}}$, and $lim_{n{\rightarrow}{\infty}}n^{-1}ES^2_n={\sigma}^2$ < ${\infty}$, then $lim_{{\epsilon}{\downarrow}0}{\epsilon}^{{2(r-p}/(2-p)-1}{\sum}^{\infty}_{n=1}n^{{\frac{r}{p}}-2-{\frac{1}{p}}}E\{{{\mid}S_n{\mid}}-{\epsilon}n^{\frac{1}{p}}\}+={\frac{p(2-p)}{(r-p)(2r-p-2)}}E{\mid}Z{\mid}^{\frac{2(r-p)}{2-p}}$, where $S_n\;=\;X_1\;+\;X_2\;+\;{\cdots}\;+\;X_n$ and Z has a normal distribution with mean 0 and variance ${\sigma}^2$.

• East Asian mathematical journal
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• 제24권3호
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• pp.251-261
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• 2008

Let {${\xi}_j;j\;{\geq}\;1$} be a centered strictly stationary random sequence defined by $S_0\;=\;0$, $S_n\;=\;\Sigma^n_{j=1}\;{\xi}_j$ and $\sigma(n)\;=\;33\sqrt {ES^2_n}$ where $\sigma(t),\;t\;>\;0$, is a nondecreasing continuous regularly varying function. Suppose that there exists $n_0\;{\geq}\;1$ such that, for any $n\;{\geq}\;n_0$ and $0\;{\leq}\;{\varepsilon}\;<\;1$, there exist positive constants $c_1$ and $c_2$ such that $c_1e^{-(1+{\varepsilon})x^2/2}\;{\leq}\;P\{\frac{{\mid}S_n{\mid}}{\sigma(n)}\;{\geq}\;x\}\;{\leq}\;c_2e^{-(1-{\varepsilon})x^2/2$, $x\;{\geq}\;1$ Under some additional conditions, we investigate some limsup results for the increments of partial sum processes of the sequence {${\xi}_j;j\;{\geq}\;1$}.

• Nonlinear Functional Analysis and Applications
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• 제27권2호
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• pp.249-259
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• 2022

Let 𝓐 be a unital C^*-algebra. Then it follows that $\sum\limits_{i=1}^{n}(a_ia^*_i)^{\frac{1}{2}}{\leq}\sqrt{n}\(\sum\limits_{i=1}^{n}a_ia^*_i\)^{\frac{1}{2}}$, ∀n ∈ ℕ, ∀a₁, …, a_n ∈ 𝓐. By modifications of arguments of Botelho-Andrade, Casazza, Cheng, and Tran given in 2019, for certain n-tuple x = (a₁, …, a_n) ∈ 𝓐ⁿ, we give a method to compute a positive element c_x in the C^*-algebra 𝓐 such that the equality $$\sum\limits_{i=1}^{n}(a_ia^*_i)^{\frac{1}{2}}=c_x\sqrt{n}\(\sum\limits_{i=1}^{n}a_ia^*_i\)^{\frac{1}{2}}$$ holds. We give an application for the integral of Kasparov. We also derive a formula for the exact constant for the continuous ℓ₁ - ℓ₂ inequality.

• 호남수학학술지
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• 제26권3호
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• pp.331-339
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• 2004

The aim of this paper is to show the difference between the notion of digital continuity and that of computer continuity. More precisely, for digital images $(X,\;k_0){\subset}Z^{n_0}$ and $(Y,\;k_1){\subset}Z^{n_1}$, $if(k_0,\;k_1)=(3^{n_0}-1,\;3^{n_1}-1)$, then the equivalence between digital continuity and computer continuity is proved. Meanwhile, if $(k_0,\;k_1){\neq}(3^{n_0}-1,\;3^{n_1}-1)$, then the difference between them is shown in terms of the uniform continuity property.

• The Korean Journal of Ecology
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• 제8권1호
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• pp.1-5
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• 1985

The plastochron index (PI) provides possibility on studies of the effects of various environmental factors on morphological and physiological development of plants. The PI of Erickson and Michemlini(1957) could be used merely when leaf n is longer an leaf n+1 is smaller than the references length at any time. If both the lengths of leaf n and n+1 are smaller or longer than the reference length, it could not estimated. In this study, the PI of Erickson and Michelini was complemented and the linear patterns according to leaf arrangement was represented, PI is n-(lnLR-lnLn)/(lnLn-lnLn+1). And when both the lengths of leaf n and n+1 are longer than the length of reference, PI is n+1+(ln Ln+1-lnLR)/(lnLn-lnLn+1). The linear model of PI is changed by the various environmental factors and the linear patterns are different according to leaf arrangement. According to leaf arrangement, the equation of the general regression lines is Yin-(i-j)=a-(n-1)(q1+...+qi-1)-(q1+...+qj-1)+rt+$\varepsilon$. Where Y:the logarithmic of the leaf length in question, i:leaf number hang on the one node, n:the number counting from base, q:spacing on the Y-axis, j:0, 1, 2, ..., r:slope, t:time, $\varepsilon$:error.

• 한국통신학회논문지
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• 제32권10C호
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• pp.959-964
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• 2007

이 논문에서는 $M|p^n-1$를 만족하는 양의 정수 M과 소수 p에 대해서 주기가 $p^n-1$인 M-진 Sidel'nikov 수열을 사용해서 M-진 수열 군을 생성하였다. 이 수열군은 상관 값의 최대간이 $3\sqrt{p^{n}}+6$을 상한으로 갖고 수열군의 크기는 p=2일 때 $(M-1)^2(2^{n-1}-1)$+M-1 이거나 p가 홀수인 소수일 때는 $(M-1)^2(p^n-3)/2+M(M-1)/2$가 된다.

• 한국결정학회지
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• 제8권2호
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• pp.132-137
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• 1997

N,N'-di-tert-butoxycabonyl-2, 7-diazabicyclo[3.3.0]oct-4-ene의 분자 및 결정구조를 X-선 회절법으로 연구하였다. 이 결정의 분자식은 C16H26N2O4, 결정계는 삼사정계이고 공간군은 P1이다. 단위세포상수 a=11.119(1) Å, b=13.638(1) Å, c=6.214(1) Å이며, α=92.14(1)°, β=103.49(1)°, γ=73.35(1)°, V=877.4(2)Å3, T=293(2)K, Z=2이다. 구조해석에 사용한 X-선은 Cu Kα선(λ=1.5418Å)이다. 구조는 직접법으로 풀었으며, 최소자승법으로 정밀화하였다. 최종 신뢰도 R값은 F0>4σ(F0)인 2389개의 독립회절데이타에 대해 5.38%이였다.

• 정보보호학회논문지
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• 제13권3호
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• pp.27-34
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• 2003

요즘 암호시스템을 효율적으로 수행하는 하드웨어의 개발이 관심의 대상이 되고 있다. 암호시스템의 효율적인 수행은 연산기의 효율적인 연산이 뒷받침되어야 한다. 특히 유한체 GF(2$^n$)에서의 곱셈기는 여러 연산 중에서 효율성이 고려되어야 할 핵심적인 연산이다. 이 논문에서는 유한체에서의 곱셈기를 시간 복잡도(time complexity)와 하드웨어복잡도(size complexity) 사이의 교환(trade-off)을 고려하여 기존 곱셈기$^{［5］［12］}$의 하드웨어 복잡도인 #AND(AND gate 수)= $n^2$, #XOR(XOR gate 수) = $n^2$-1 보다 개선된 #AND = [n/2], #XOR = n([n/2+1])-$\delta$$_{n}$ (n이 짝수이면$\delta$$_{n}$ =1, n이 홀수이면 $\delta$n=0)이고 두 클럭 내에 결과를 얻을 수 있는 직렬-병렬 곱셈기를 제안한다. 우리는 기존의 논문에서 제안된 곱셈기와 구조를 달리하여 공간의 제약이 있는 하드웨어에 적합한 효율적인 연산기의 구현방안을 제시한다.

• 한국마린엔지니어링학회:학술대회논문집
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• 한국마린엔지니어링학회 2001년도 추계학술대회 논문집(Proceeding of the KOSME 2001 Autumn Annual Meeting)
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• pp.112-119
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• 2001

Parameter tuning methods by Ziegler-Nickels for control systems are generally classified into Z-N(1) and Z-N(2). The purpose of this paper is to describe what relations exist between methods of Z-N(1) and Z-N(2), or how Z-N(1) method can be originated from Z-N(2) method by analyzing one loop control system of P or PI controller and time delay process. The formulas of Z-N(1) consist of process parameters, L(time delay), $K_m$(gain) and $T_m$(time constant), but Z-N(2) method is based only on the ultimate gain $K_u$ and the ultimate period $T_u$ acquired normally by practical trial without any parameters of Z-N(1). In this paper, for the first step to seek mutual relations, the simple formulas of Z-N(2) are transformed into the formulas composed of the same parameters as Z-N(1) which is derived from the analysis of frequency characteristics. Then, the approximation of the actual ultimate frequency is proposed as important premise in the translation between Z-N(1) and (2). Such equalization and approximation brings a simple approximated formula which can explain how Z-N(1) is originated from the Z-N(2) in the form of formula. And a model system is adopted to compare the approximated formula to Z-N(1) and Z-N(2) methods, the results of which show the effectiveness of the proposals.

• 대한수의학회지
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• 제47권3호
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• pp.273-279
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• 2007

Swine influenza is an acute, infectious respiratory disease caused by type A influenza viruses in pigs. In the previous studies, serological surveys have indicated the presence of H3N2 swine influenza virus (SIV) since 1995 in Korea. And the percentage of the antibody-positive rate was 39.12% in the survey determining the prevalence of H1N1 SIV antibodies in 2002. The purpose of this study was therefore to investigate the sero-prevalence of SIV regard to the age of the pig and the season between June 2004 and May 2005. In this study, a total of 932 sera were used. These sera were randomly selected from blood samples, which were submitted to Department of Veterinary Pathology, Kangwon National University and Department of Veterinary Virology, Seoul National University from June 2004 to May 2005. These sera have been tested by ELISA test kit (IDEXX Lab, USA) for the SIV H3N2, H1N1 respectively. SAS version 9.1 was used for the statistical analysis based on the age of the pig and the season. The overall sero-prevalence of the antibody against H3N2 SIV was 20.82% (194/932). The overall sero-prevalence of the antibody against H1N1 SIV was 37.23% (347/932). The overall dual sero-prevalence of the antibody against H3N2 and H1N1 SIV was 10.62% (99/932). H3N2 has significant difference in statistically regarding the age of the pig and the season (p<0.0001). H1N1 has significant difference in statistically regarding the age of the pig (p<0.0001) but has not significant difference in statistically regarding the season (p=0.5882).