具强连续时滞P—P系统中的非定常周期解

本文研究具有连续时滞的捕食一被捕食系统=x:(￡,一a lx;一了,万:)(1)X.︸了.龟.气二.飞XZ=XZ(-￡2一+:2 11_F(卜·)一(·)“一其中,x,,x:分别表示被捕食种群和捕食种群的密度,:,a,了}>。,:二1,2F(t)》o。JF(t)dr=了.文(1〕研究了当核函数F(t)=。。一“’时的情形,也就是对应于弱时滞的情形。本文7礴曹贤通S卷则研究当核函数F(丈)=a’t‘‘’时的情形,也就是对应于强时滞的情形 引入变量F;(t一丁)x,(r)d丁,一O(,月.1李 一一 3 XF(t一T)x;(r)dT,一O乙,力‘..J 一一 J吸 X这里F:(r)=ae一‘’,F(t)=aZte一‘’系统(1)等价于二xx(￡1…     

种群模型参数辨识的一种方法

1、M(。,m)模型的建立定理.对于微分方程 dnx,(t)dtn+口zd卜lx,(t) dtn一1+…+a。_:dx:(t) dt否,x,(‘)+box:(‘)+b3x;(‘)x:(‘)+…+”。·,x:(‘)‘二(‘)给定样本数据{x;(k)1,k二1,2,…,N,i=I,2,…,m,则该方程的参数向量a=〔a:aZ…a。一,ib:bZ…b二+:〕丁可通过〔(AIB)T(A{B)〕一’(A{B)TC辨识,其中,C=〔△,x;(2),△nx:(了),…,△。x,(N)〕T陈华豪等万卷s2/△,一‘x工(2)△“一‘x:(3)…△x:(2)△x:(3)A二一……△一’x,(N),△x,(、){,111\x,(z),x贯(1),x,(1)x:(1),…,x;(了).x二(I)B二‘1‘“’,‘飞‘”,‘1.:员.,‘2‘2’,”…     

中立型时滞LOTKA—VOLTERRA系统解的稳定性和振动性

一、引言考虑中立型时滞Lotka-Volterra系统 (t)=N(t)[a_i-sum from j=1 to n b_(ij) N_i(t—τ_(ij))-sum from j=1 to n c_(ij) (t-σ_(ij))],i=1,2,…,n,(E)其中τ_(ij),σ_(ij)∈(0,∞),a,b_(ij),c_(ij)∈R,i,j=1,2,…,n,对正常数平衡点N~*的稳定性和振动性。由于系统(E)是描述种群所组成的生态群落中种群之间互相作用的生态     

害虫,天敌和食料的数学模型

本文从实际问题出发,结合已有的描述群落生态的数学模型,提出了一组描述马尾松毛虫(Dendrolimus pnnctalus,walker)、条毒蛾(Lymantria dissoluta,Swinhoe)、天敌和食料之间动态关系的数学模型: w(k+1=(a_1x(k+1)/(1+a_2x(k+1)/_z(k))+a_3w(k)/(1+a_4w(k)/y(k)) x(k+1)=b_1w(k)/(1+b_2w(k)/y(k))+b_3x(k)/(1+b_4x(k)/z(k))+ y(k+1)=c_1z(k)/[1+c_sz(k)+c_3y(k)][1+c_4w(k)+(k+1)] z(k+1)=d_1z(k)/[1+d_2z(k)][1+d_3x(k)+d_4w(k)] 对于这个模型的线性化形式,详细讨论了控制松毛虫的暴发所需的条件及其生态学机制。     

应用T/B～[Ag]线性方程式求抗原决定簇数目

本文根据作者曾报道的放射免疫定量测定的线性方程式T/B=(n[~*Ag]_0)/(2[Ab]_0) n/(2[Ab]_0)[Ag]_■,采用经改良过的放射对流免疫定量电泳法,可在较短的时间内直接测定出抗原参加免疫化学反应的平均抗原决定簇数目n。实验测得猪胰岛素n_(InS)=1.5,人血清白蛋白n_(HSA)=16,人甲胎蛋白n_(FP)=6,乙型肝炎病毒表面抗原n_(HBsAg)=145。并对所测得的n 值结合各自的物理化学性质进行了讨论。     

加拿大一枝黄花入侵的细胞学机制

对入侵植物加拿大一枝黄花(Solidago canadensis L.)和同属土著种一枝黄花(Solidago decurrens Lour.)的染色体计数,并对核型进行了分析.实验结果:加拿大一枝黄花染色体数目为2n=54,核型公式为k(2n)=6x=54＝46m 8sm(0-6SAT),核型类型为2A型;一枝黄花染色体数目为2n=18,核型公式为k(2n)=2x=18=16m 2sm(0-2SAT),核型类型为1A型.通过对一枝黄花属(Solidago L.)植物染色体数目的统计分析,判断该属的染色体基数为9.通过对多倍体基因表达导致植物适应进化的讨论得出:多倍体是入侵植物特征,可能是植物入侵的内在机制.     

种群生态系统的持续生存

一、引言许多描述种群生态的数学模型都可以由一常微分方程组 x＇=f(x) (x＇=dx/dt) (1.1)来描述。这里, x=(x_1,x_2,…,x_1)~T∈R_+~n,t∈R_+,R_+~n={x|x≥0,i=1,2,…,n},R_+={t|t≥0},f(x)=〔f_1(x),f_2(x),…,f_2(x)〕~T,x_i表示种群的数量或密度。记intR_+~n为R_+~n的内部,bdR_+~n为RR_+~n的边界。对于一个生态系统,我们通常最关心的是生态平衡问题,这就需要研究系统(1.1)的动力学行为。对于系统(1.1)而言,若存在正平衡位置,且它相对于intR_+~n是全局渐近稳定     

L2[o,r2]上的人口算子

用LZ〔0,:。〕表示通常意义下的Hilbert空间.在空间L“〔0,1。〕中,人口发展算子A“2’定义如下:定义域。‘A,={。‘·,卜‘·,dP(了) dr一“(r)p(,)〔LZ〔o,:,〕;p(o)_。f犷,,_,.,、:,_、*,_、J_1、*‘_、二。,,、‘,*、‘_、__dp(:)=夕l无(r)h(了)户(,)d了卜对p(1)〔D(A),(AP)(7)=一丝书井三 rJ九一’一“一’J‘一‘一’dT一“(r)P(犷),其中,1。为社会中人能活到的最大年龄,〔;,,12〕为妇女育龄区间,h(1)表示生育模式,k(下)表示女性比例函数,那(犷)表示相对死亡率,口>o为妇女总和生育率.拼(r),k(了),h(了)满足下面条件(I).召(,),…     

美在洛克路

2223B。。。:怒赢…。。,- .j彳一。一0j磁0¨j’凄豢浚一一:。_.;。_’?;l冬,～’∥群黪黪瓣豁冀:一翁菩蕤趋壤囊辐。鲢t亚丁红草地李非摄糕≯棼¨≯嘤p√够『i;’■|lj藕擎矿—■一一t f ’f。‘L j二日盛强鑫∥‰霈’《洒满阳光的小径李非摄亚丁金秋李非摄一I生:eauty of wildness氛夏洛多吉雪山李非摄美在洛克路     

利用AABBDDDD八倍体培育小麦-簇毛麦二体附加系的研究

对普通小麦（Triticumaestivum）-节节麦（Aegilopssquarrosa）八倍体（2n=8x=56,AABBDDDD）与硬粒小麦（Triticumdurum）-簇毛麦（Haynaldiavillosa）六倍体（2n=6x＝42,AABBVV）杂交后,将所得七倍体杂种（AABBDDV）进行连续自交,在F4代中利用C-分带鉴定出可能的簇毛麦6V二体附加系95－7和2V二体附加系26－7,其花粉母细胞染色体在减数分裂中期I的配对构型分别为0.14I＋20．42＋1．5和0．10I＋20．07＋1.82;进一步将95－7和26－7的基因组DNA用EcoRI酶切,分别用小麦族第6部分同源群短臂探针Psr113和第2部分同源群长臂探针BCD240进行Southern杂交,结果显示具有簇毛麦的特异杂交带,进一步确证了95－7和26－7分别是普通小麦-簇毛麦6V和2V二体附加系。     

Compound Intervened Poisson Distribution

The nature and characteristics of Intervened Poisson Distribution (IPD) has been well discussed by Shanmugam (1985). In this paper, Compound Intervened Poisson Distribution (CIPD) is introduced and its properties are studied.     

林木分布格局多样性测度方法: 以阔叶红松林为例

林木分布格局是森林结构的重要组成部分, 直接影响森林生态系统的健康与稳定, 维持森林结构多样性被认为是保护生物多样性的最佳途径。本研究探讨了林木分布格局多样性的测度方法, 以期为揭示森林结构多样性提供理论依据。格局多样性研究的关键在于选择合适的生物多样性测度方法和具有分布属性的格局指数。本研究通过统计角尺度分布频率和Voronoi多边形边数分布频率, 运用Simpson指数分别计算角尺度多样性和Voronoi多边形边数分布多样性, 作为表达林木分布格局多样性指数的方法, 并以我国东北吉林蛟河的3个100 m × 100 m的阔叶红松(Pinus koreansis)林长期定位监测标准地为例, 分析了林木分布格局的多样性。结果表明: 无论是角尺度分布还是Voronoi多边形的边数分布都接近正态分布, 角尺度分布中随机分布林木的频数最多, 占55%以上; Voronoi多边形的类型多达10个以上, 50%以上的林木有5-6株最近相邻木。利用Simpson指数衡量林木格局多样性, 角尺度分布与Voronoi多边形的边数分布都显示出聚集分布的林分比随机分布林分的格局多样性高。研究还发现, 两种格局判定方法得出的Simpson指数值有所不同, 角尺度分布的多样性数值明显低于Voronoi多边形的边数分布的多样性数值, 主要原因是二者的等级数量不同。可见, 林木分布格局多样性研究应选择具有分布属性的格局指数, 但由于各指数反映的角度不同, 所以在分析比较不同林分格局多样性时应采用相同的分析方法。     

白三叶草生长期西花蓟马的空间分布型变化

利用聚集度指标检验和比较频次法对白三叶草Trifolium repens生长期间西花蓟马Frankliniella occidentalis的空间分布型变化进行研究,结果如下：聚集度指标检验分析表明西花蓟马在白三叶草上的空间分布为聚集分布;利用频次拟合分析表明白三叶草上大部分生长期内其分布型为负二项分布,其聚集程度与虫口密度有关系,其空间分布不会因为一些人为干扰而改变。     

中国龟鳖动物的分布

本文依据1997年以来的文献,对中国龟鳖动物新增加的分布作了归纳和讨论;并对中国龟鳖动物的分布区系及特征作了初步分析和总结.     

栲属(壳斗科)植物的现代和地史分布

根据文献资料和标本馆及化石记录,讨论了壳斗科栲属植物的现代分布和地史分布。现代栲属植物有110～134种,主要分布在东亚及东南亚,其中印度支那地区有82种栲属植物,是世界栲属植物分布最集中的地区,马来西亚地区是栲属特有种最丰富的事实是支持马来西亚地区与其它地区的区系交流十分有限的论据。中国栲属植物最丰富的地区是滇黔桂地区（29种）。栲属植物现代多样化中心在马来西亚和中南半岛。排除Chrysolepis后,栲属的分布类型应属热带亚洲分布。栲属在地质历史上有着比现在广泛的分布,最早、最可靠的栲属化石记录发现于北美始新世地层,欧洲和日本始新世也有栲属的化石记录,化石记录表明栲属起源的时间不晚于古新世,所有的壳斗科及栲属的化石都发现于北半球,现代分布也主要在北半球,壳斗科及栲属起源于北半球可以确认,由于化石证据与现代植物学的研究结果有较大差异以及关键地区化石证据的不足,具体的起源地尚不能肯定。     

Modelling potential biotope composition on a regional scale revealed that climate variables are stronger drivers than soil variables

Aim

Environmental conditions define the suitability of an area for biotopes, and any area can be suitable for several biotopes. However, most previous studies modelled the distribution of single biotopes ignoring the potential co-occurrence of biotopes in one area, which limits the usefulness of such models for conservation and restoration planning. In this study, we described the potential biotope composition of an area in response to environmental conditions.

Location

Bavaria, Federal State of Germany.

Methods

Based on the Bavarian biotope mapping data, we modelled the distribution of 29 terrestrial biotopes based on six climate variables and six chemical and four physical soil properties using the species distribution modelling algorithm Maxent.

Results

For most biotopes, we found that climate variables were more important than soil variables for the biotope distribution and that the area of the predicted biotope distribution was larger than the observed distribution. The potential biotope composition illustrated that while 8% of the area in Bavaria was not sufficiently suitable for any analysed biotope, 92% of the modelled area in Bavaria was suitable for at least one biotope, 84% for two and 77% for at least three biotopes. The difference in suitability between the most suitable biotopes in composition was minor. Further, over one-quarter of the modelled area was suitable for 6–8 different biotopes.

Main Conclusions

Our study showed that considering a composition of potentially suitable biotopes in a raster cell, instead of only the most suitable biotope, provides valuable information to identify conservation priorities and restoration opportunities.     

Maximum-entropy calculation of free energy distributions for two forms of myoglobin

The temperature dependence of the heat capacity of myoglobin depends dramatically on pH. At low pH (near 4.5), there are two weak maxima in the heat capacity at low and intermediate temperatures, respectively, whereas at high pH (near 10.7), there is one strong maximum at high temperature. Using literature data for the low-pH form (Hallerbach and Hinz, 1999) and for the high-pH form (Makhatadze and Privalov, 1995), we applied a recently developed technique (Poland, 2001d) to calculate the free energy distributions for the two forms of the protein. In this method, the temperature dependence of the heat capacity is used to calculate moments of the protein enthalpy distribution function, which in turn, using the maximum-entropy method, are used to construct the actual distribution function. The enthalpy distribution function for a protein gives the fraction of protein molecules in solution having a given value of the enthalpy, which can be interpreted as the probability that a molecule picked at random has a given enthalpy value. Given the enthalpy distribution functions at several temperatures, one can then construct a master free energy function from which the probability distributions at all temperatures can be calculated. For the high-pH form of myoglobin, the enthalpy distribution function that is obtained exhibits bimodal behavior at the temperature corresponding to the maximum in the heat capacity (Poland, 2001a), reflecting the presence of two populations of molecules (native and unfolded). For this form of myoglobin, the temperature evolution of the relative probabilities of the two populations can be obtained in detail from the master free energy function. In contrast, the enthalpy distribution function for the low-pH form of myoglobin does not show any special structure at any temperature. In this form of myoglobin the enthalpy distribution function simply exhibits a single maximum at all temperatures, with the position of the maximum increasing to higher enthalpy values as the temperature is increased, indicating that in this case there is a continuous evolution of species rather than a shift between two distinct population of molecules.     

On the HIV Incubation Distribution Under AZT Treatment

Assuming some general models for the HIV epidemic, in this paper I derive the HIV incubation distributions under AZT treatment. It is shown that under some conditions, these probability distributions are mixtures of some generalized Gamma distributions and products of generalized Gamma distributions.     

A generalizing,analytic model for 2-way cross-classifications. extensions and ramifications. part 1

A generalizing, analytic model is developed for 2-way cross-classifications with fixed class sizes The model is expressed in closed form as a simple operator formula, and is readily extended to n-way cross-classifications, and to such cases where one or more cells are vacuous or fixed. The model permits easy derivation, by means of simple differential operators, of the exact power moments, product moments, and factorial moments of the cell frequencies. From this, the moments of the exact sampling distribution of the conventional x₂-statistic can be computed, which, in turn, leads to a reappraisal of the Chi-square approximation for sparse and isotropic contingency tables. Here, the Gamma distribution is considered, and numerical results are presented that would suggest preference of the Gamma approximation over the Chi-square in such cases.     

Limits to the estimation of species richness: The use of relative abundance distributions

The present study demonstrates the possibility of estimating species numbers of animal or plant communities from samples using relative abundance distributions. We use log‐abundance–species‐rank order plots and derive two new estimators that are based on log‐series and lognormal distributions. At small to moderate sample sizes these estimators appear to be more precise than previous parametric and nonparametric estimators. We test our estimators using samples from 171 published medium‐sized to large animal and plant communities taken from the literature. By this we show that our new estimators define also limits of precision.