Appendix 1: Asymptotic Expression for \({\bf{\Pr _1^{out}}}\)
We note that the \({{\textit{SNR}}_{SR_1^i}}(i \in \{1,2,\ldots ,{N_1}\}\) are not mutually independent because they belong to the same RVs \(|{h_{SP}}{|^2}\). From (2) and (3), the probability of the decoding set \({C_1}\) is formulated as follows:
$$\begin{aligned} \Pr \left[ {{C_1}\left| {|{h_{SP}}{|^2}} \right. } \right] &= \prod \limits _{p = 1}^{{m_1}} {\Pr }\, \left[ {\min \, \left( {{P_{th}}|{h_{SR_1^p}}{|^2},{I_P}{\frac{{|{h_{SR_1^p}}{|^2}}}{{|{h_{SP}}{|^2}}}}} \right) \ge {{\textit{SNR}}_{th}}{N_0}} \right] \\ &\quad \times \, \prod \limits _{q = {m_1} + 1}^{{M_1}} {\Pr }\,\left[ {\min \, \left( {{P_{th}}|{h_{SR_1^qS}}{|^2},{I_P}{\frac{{|{h_{SR_1^q}}{|^2}}}{{|{h_{SP}}{|^2}}}}} \right) < {{\textit{SNR}}_{th}}{N_0}} \right] \end{aligned}$$
(20)
We divide the Eq. (20) into two cases as \(|{h_{SP}}{|^2} < {\frac{{{I_P}}}{{{P_{th}}}}}\) and \(|{h_{SP}}{|^2} > {\frac{{{I_P}}}{{{P_{th}}}}}\):
$$\begin{aligned} \Pr \left[ {{C_1}\left| {|{h_{SP}}{|^2}} \right. } \right] = \left[ \begin{array}{ll} \left\{ \begin{array}{ll} \prod \limits _{p = 1}^{{m_1}} {\Pr } \left[ {|{h_{SR_1^p}}{|^2} \ge {\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right] \\ \quad \times \prod \limits _{q = {m_1} + 1}^{{M_1}} {\Pr } \left[ {|{h_{SR_1^q}}{|^2} < {\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right] \end{array} \right. \quad if \, |{h_{SP}}{|^2} < {\frac{{{I_P}}}{{{P_{th}}}}}\\ \left\{ \begin{array}{ll} \prod \limits _{p = 1}^{{m_1}} {\Pr }\, \left[ {\frac{{|{h_{SR_1^p}}{|^2}}}{{|{h_{SP}}{|^2}}} \ge {\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{I_P}}}}} \right] \\ \quad \times \prod \limits _{j = {k_1} + 1}^{{N_1}} {\Pr }\, \left[ {\frac{{|{h_{SR_1^q}}{|^2}}}{{|{h_{SP}}{|^2}}} < {\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{I_P}}}}} \right] \end{array} \right. \quad if \,|{h_{SP}}{|^2} > {\frac{{{I_P}}}{{{P_{th}}}}} \end{array} \right. \end{aligned}$$
(21)
The probability density function (PDF) and the cumulative distribution function (CDF) of RVs \(|{h_{SR_1^i}}{|^2}\) are respectively given as:
$${f_{_{\left|{h_{SR_1^i}}\right|^2}}}(x)= {\lambda _{S{R_1}}}\exp \left( {- {\lambda _{S{R_1}}}x} \right)$$
(22)
$${F_{_{\left|{h_{SR_1^i}}\right|^2}}}(x)= 1 - \exp \left( {- {\lambda _{S{R_1}}}x} \right)$$
(23)
Then, we have the following probabilities:
$$\Pr \left[ {\left|{h_{SR_1^i}}\right|^2 \le x} \right]= {F_{_{|{h_{SR_1^i}}{|^2}}}}(x)$$
(24)
$$\Pr \left[ {\left|{h_{SR_1^i}}\right|^2 > x} \right]= 1 - {F_{{\left|{h_{SR_1^i}}\right|^2}}}(x)$$
(25)
Substituting (24) and (25) into (21), we obtain as
$$\begin{aligned} \Pr \left[ {{C_1}\left| {|{h_{SP}}{|^2}} \right. } \right] = \left[ \begin{array}{ll} \left\{ \begin{array}{ll} \prod \limits _{p = 1}^{{m_1}} {\left[ {1 - {F_{\left|{h_{SR_1^p}}\right|^2}}\left( {\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}} \right) } \right] } \\ \quad \times \prod \limits _{q = {m_1} + 1}^{{M_1}} {{F_{\left|{h_{SR_1^q}}\right|^2}}\left( {\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}} \right) } \end{array} \right. \quad if\,|{h_{SP}}{|^2} < {\frac{{{I_P}}}{{{P_{th}}}}}\\ \left\{ \begin{array}{ll} \prod \limits _{p = 1}^{{m_1}} {\left[ {1 - {F_{\left|{h_{SR_1^p}}\right|^2}}\left( {\frac{{{{\textit{SNR}}_{th}}{N_0}|{h_{SP}}{|^2}}}{{{I_P}}}} \right) } \right] } \\ \quad \times \prod \limits _{q = {m_1} + 1}^{{M_1}} {{F_{\left|{h_{SR_1^q}}\right|^2}}\left( {\frac{{{{\textit{SNR}}_{th}}{N_0}|{h_{SP}}{|^2}}}{{{I_P}}}} \right) } \end{array} \right. \quad if\,|{h_{SP}}{|^2} > {\frac{{{I_P}}}{{{P_{th}}}}} \end{array} \right. \ \end{aligned}$$
(26)
Substituting (22) and (23) into (26), we obtain as
$$\begin{aligned} \Pr \, \left[ {{C_1} \left| {|{h_{SP}}{|^2}} \right. } \right] = \left[ \begin{array}{ll} \left\{ \begin{array}{ll} \exp \left( { - {m_1}{\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right) \\ \quad \times {\left( {1 - \exp \left( {- {\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right) } \right) ^{{M_1} - {m_1}}} \end{array} \right. \quad if\,|{h_{SP}}{|^2} < {\frac{{{I_P}}}{{{P_{th}}}}}\\ \left\{ \begin{array}{ll} \exp \left( { - {m_1}{\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}|{h_{SP}}{|^2}}}{{{I_P}}}}} \right) \\ \quad \times {\left( {1 - \exp \left( {- {\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}|{h_{SP}}{|^2}}}{{{I_P}}}}} \right) } \right) ^{{M_1} - {m_1}}} \end{array} \right. \quad if\,|{h_{SP}}{|^2} > {\frac{{{I_P}}}{{{P_{th}}}}} \end{array} \right. \end{aligned}$$
(27)
Let X be an i.i.d. exponential RV with parameter \({\lambda _{SP}}\), the probability for choosing decoding set \({C_1}\) is obtained as
$$\Pr \left[ {{C_1}} \right] = {\int _0^{+ \infty } {\Pr \left[ {{C_1}\left| x \right. } \right] \times f} _X}(x)dx$$
(28)
From (27) and (28), we obtain:
$$\begin{aligned} \Pr \left[ {{C_1}} \right] &= \exp \left( {- {m_1}{\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right) \times {\left( {1 - \exp \left( { - {\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right) } \right) ^{{M_1} - {m_1}}}\\ &\quad \times \, \int _0^{\frac{{{I_P}}}{{{P_{th}}}}} {{\lambda _{SP}}} \exp ( - {\lambda _{SP}}x)dx + \int _{\frac{{{I_P}}}{{{P_{th}}}}}^{+ \infty } {\left\{ {\exp \left( { - {m_1}{\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}x}}{{{I_P}}}}} \right) } \right. } \\ &\quad \times \, \left. {{{\left( {1 - \exp \left( {- {\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}x}}{{{I_P}}}}} \right) } \right) }^{{M_1} - {m_1}}} \times {\lambda _{SP}}\exp ( - {\lambda _{SP}}x)dx} \right\}\end{aligned}$$
(29)
From [11, chapter 4], we have the asymptotic expansion of the exponential function as follows
$${e^x}\mathop = \limits _{x \rightarrow 0} 1 + x + {\frac{{{x^2}}}{2}} + {\frac{{{x^3}}}{6}} + O({x_4})$$
(30)
When \(\theta = {\frac{1}{{{N_0}}}} \rightarrow \infty\) or \({{\textit{SNR}}_{th}}{N_0} \rightarrow 0\), from (30) we have the asymptotic expression as:
$$\exp \left( {- {\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right) = 1 - {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}}{{\textit{SNR}}_{th}}{N_0} + O\left( {{{\left[ {- \frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}{{\textit{SNR}}_{th}}{N_0}} \right] }^2}} \right)$$
(31)
From (31), we have the approximate expression as follows
$$1 - \exp \left( {- {\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}}}{{{P_{th}}}}}} \right) \approx {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}}{{\textit{SNR}}_{th}}{N_0}$$
(32)
Similar to (32), we also obtained as
$$1 - \exp \left( {- {\lambda _{S{R_1}}}{\frac{{{{\textit{SNR}}_{th}}{N_0}x}}{{{I_P}}}}} \right) \approx {\frac{{{\lambda _{SR}}x}}{{{I_P}}}}{{\textit{SNR}}_{th}}{N_0}$$
(33)
Substituting (32) and (33) into (29), we obtain the asymptotic expression of \(\Pr [{C_1}]\) when \(\theta \rightarrow \infty\) or \({{\textit{SNR}}_{th}}{N_0} \rightarrow 0\) as follows
$$\begin{aligned} \Pr _{S{R_1}}^{out} &= {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}{{\textit{SNR}}_{th}}{N_0}} \right) ^{{M_1} - {m_1}}} \times \int _0^{\frac{{{I_P}}}{{{P_{th}}}}} {{\lambda _{SP}}} \exp ( - {\lambda _{SP}}x)dx\\ &\quad +\, \int _{\frac{{{I_P}}}{{{P_{th}}}}}^{+ \infty } {{{\left( {\frac{{{\lambda _{S{R_1}}}x}}{{{I_P}}}{{\textit{SNR}}_{th}}{N_0}} \right) }^{{M_1} - {m_1}}} \times {\lambda _{SP}}} \exp ( - {\lambda _{SP}}x)dx \end{aligned}$$
(34)
By using the Eq. 3.381.3 in Gradshteyn and Tadzhik [12]: \(\int _u^\infty {{x^{v - 1}}\exp ( - \mu x)dx} = {\mu ^{- v}}\varGamma (v,\mu u)\), we obtain the followings result:
$$\begin{aligned} & \int _{\frac{{{I_P}}}{{{P_{th}}}}}^{+ \infty } {{{\left( {\frac{{{\lambda _{S{R_1}}}x}}{{{I_P}}}{{\textit{SNR}}_{th}}{N_0}} \right) }^{{M_1} - {m_1}}}{\lambda _{SP}}} \exp ( - {\lambda _{SP}}x)dx\\ &\quad = {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}}}{{\textit{SNR}}_{th}}{N_0}} \right) ^{{M_1} - {m_1}}}{\lambda _{SP}}{\left( {{\lambda _{SP}}} \right) ^{- \left( {{M_1} - {m_1} + 1} \right) }}\varGamma \left( {{M_1} - {m_1} + 1,{\frac{{{I_P}{\lambda _{SP}}}}{{{P_{th}}}}}} \right) \\ &\quad = {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}{\lambda _{SP}}}}} \right) ^{{M_1} - {m_1}}}\varGamma \left( {{M_1} - {m_1} + 1,{\frac{{{I_P}{\lambda _{SP}}}}{{{P_{th}}}}}} \right) {\left( {{{\textit{SNR}}_{th}}{N_0}} \right) ^{{M_1} - {m_1}}} \end{aligned}$$
(35)
Substituting (35) into (34), we obtain
$$\begin{aligned} \Pr \left[ {{C_1}} \right] \ &= {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}} \right) ^{{M_1-m_1}}}\left( {1 - \exp \left( {- \frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}} \right) } \right) {\left( {{{\textit{SNR}}_{th}}{N_0}} \right) ^{{M_1-m_1}}}\\ &\quad +\, {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}{\lambda _{SP}}}}} \right) ^{{M_1-m_1}}}\varGamma \left( {{M_1-m_1} + 1,{\frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}}} \right) {\left( {{{\textit{SNR}}_{th}}{N_0}} \right) ^{{M_1-m_1}}}\\ &= \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}} \right) ^{{M_1-m_1}}}\left( {1 - \exp \left( {- \frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}{\lambda _{SP}}}}} \right) ^{{M_1-m_1}}}\varGamma \left( {{M_1-m_1} + 1,{\frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^{{M_1}-m_1}} \end{aligned}$$
(36)
where \(\varGamma \left( {.,.} \right)\) is the incomplete upper gamma function [12].
From (36), we have the probability of decoding set \({C_1}\) when \({m_1} = 0\):
$$\begin{aligned} \Pr _{S{R_1}}^{out} &= \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}} \right) ^{{M_1}}}\left( {1 - \exp \left( {- \frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}{\lambda _{SP}}}}} \right) ^{{M_1}}}\varGamma \left( {{M_1} + 1,{\frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^{{M_1}}}\\ &= {X_1} \times {\theta ^{- {M_1}}} \end{aligned}$$
(37)
which \(X_1\) is denoted as
$$\begin{aligned} {X_1} = \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}} \right) ^{{M_1}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}{\lambda _{SP}}}}} \right) ^{{M_1}}}\varGamma \left( {{M_1} + 1,{\frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {{{\textit{SNR}}_{th}}} \right) ^{{M_1}}} \end{aligned}$$
From (37), the outage probability of the links \({{\textit{CR}}_1} - {{\textit{CR}}_2}\) and \({{\textit{CR}}_2} - D\) can be formulated similar to that of the \(S - {{\textit{CR}}_1}\) link due to the independence of these three links:
$$\begin{aligned} Pr _{{R_1}{R_2}}^{out}&= \left[ \begin{array}{ll} \left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{P_{th}}}}} \right) ^{{M_2}}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{I_P}{\lambda _{{R_1}P}}}}} \right) ^{{M_2}}}\varGamma \left( {{M_2} + 1,{\frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^{{M_2}}} \\ &= {X_2} \times {\theta ^{ - {M_2}}} \end{aligned}$$
(38)
$$\begin{aligned} \Pr _{{R_2}D}^{out}= & \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{P_{th}}}}} \right) ^1}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{I_P}{\lambda _{{R_2}P}}}}} \right) ^1}\varGamma \left( {1 + 1,{\frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^1} \\=\, & {X_3} \times {\theta ^{ - 1}} \end{aligned}$$
(39)
where \(X_2\) and \(X_3\) are given as
$$\begin{aligned} {X_2}= & \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{P_{th}}}}} \right) ^{{M_2}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{I_P}{\lambda _{{R_1}P}}}}} \right) ^{{M_2}}}\varGamma \left( {{M_2} + 1,{\frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {{{\textit{SNR}}_{th}}} \right) ^{{M_2}}}\\ {X_3}= & \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{P_{th}}}}} \right) ^1}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{I_P}{\lambda _{{R_2}P}}}}} \right) ^1}\varGamma \left( {1 + 1,{\frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {{\textit{SNR}}_{th}} \end{aligned}$$
In addition, at high \(\theta\) value \(\left( {{{\textit{SNR}}_{th}}{N_0} \rightarrow 0} \right)\), we can approximate an expression for \(\Pr _1^{out}\) as
$$Pr_1^{out} = Pr _{S{R_1}}^{out} + Pr _{{R_1}{R_2}}^{out} + Pr _{{R_2}D}^{out} = {X_1}{\theta ^{ - {M_1}}} + {X_2}{\theta ^{ - {M_2}}} + {X_3}{\theta ^{ - 1}}$$
(40)
From [13, Eq. (3)], the diversity gain is calculated as follows
$${D_1} = - \mathop {\lim }\limits _{\theta \rightarrow + \infty } {\frac{{\log \left( {\Pr _1^{out}} \right) }}{{\log \theta }}}$$
(41)
From (40) and (41), the diversity gain of the NCT protocol is obtained as
$$\begin{aligned} {D_1} = - \mathop {\lim }\limits _{\theta \rightarrow + \infty } {\frac{{\log \left( {{X_1} \times {\theta ^{ - {M_1}}} + {X_2} \times {\theta ^{ - {M_2}}} + {X_3} \times {\theta ^{ - 1}}} \right) }}{{\log \theta }}}\\ \,\,\,\,\,\,\,\,\,\,= - \max \left( { - {M_1}, - {M_2}, - 1} \right) = 1 \end{aligned}$$
(42)
Appendix 2: Asymptotic Expression for \({\bf{\Pr _2^{out}}}\)
We have the end-to-end outage probability for the CT3H protocol as in (16):
$$P_2^{out} = \sum \limits _{{m_1} = 0}^{{M_1}} {C_{{M_1}}^{{m_1}}} \Pr \left[ {{C_1}} \right] \sum \limits _{{m_2} = 0}^{{M_2} \times {m_1}} {C_{{M_2} \times {m_1}}^{{m_2}}} \Pr \left[ {{C_2}} \right] \ (Pr _{{R_2}D}^{out})^{{m_2}}$$
(43)
From (33), we obtain the result of \(\sum \nolimits _{{m_1} = 0}^{{M_1}} {C_{{M_1}}^{{m_1}}} \Pr \left[ {{C_1}} \right]\) as follows:
$$\begin{aligned} \sum \limits _{{m_1} = 0}^{{M_1}} {C_{{M_1}}^{{m_1}}} \Pr \left[ {{C_1}} \right] &= \sum \limits _{{m_1} = 0}^{{M_1}} {C_{{M_1}}^{{m_1}}} \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}} \right) ^{{M_1} - {m_1}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}{\lambda _{SP}}}}} \right) ^{{M_1} - {m_1}}}\varGamma \left( {{M_1} - {m_1} + 1,{\frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] \\ &\quad \times \, {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^{{M_1} - {m_1}}}\\ &= \sum \limits _{{m_1} = 0}^{{M_1}} {C_{{M_1}}^{{m_1}}} {X_4}{\theta ^{ - ({M_1} - {m_1})}} \end{aligned}$$
(44)
where \(X_4\) is denoted as
$$\begin{aligned} {X_4} = \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{P_{th}}}}} \right) ^{{M_1} - {m_1}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{S{R_1}}}}}{{{I_P}{\lambda _{SP}}}}} \right) ^{{M_1} - {m_1}}}\varGamma \left( {{M_1} - {m_1} + 1,{\frac{{{\lambda _{SP}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {{{\textit{SNR}}_{th}}} \right) ^{{M_1} - {m_1}}} \end{aligned}$$
Also, we can obtain
$$\begin{aligned} &\sum \limits _{{m_2} = 0}^{{M_2} \times {m_1}} {C_{{M_2} \times {m_1}}^{{m_2}}} \Pr \left[ {{C_2}} \right] = \sum \limits _{{m_2} = 0}^{{M_2} \times {m_1}} {C_{{M_2} \times {m_1}}^{{m_2}}} \\ &\quad \times \, \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_1}\,{R_2}}}}}{{{P_{th}}}}} \right) ^{{M_2} \times {m_1} \,-\, {m_2}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_1}\,P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_1}\,{R_2}}}}}{{{I_P}{\lambda _{{R_1}\,P}}}}} \right) ^{{M_2} \times {m_1}\, -\, {m_2}}}\varGamma \,\left( {{M_2}\, - \,{m_2}\, +\, 1,{\frac{{{\lambda _{{R_1}\,P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] \\ &\quad \times \, {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^{{M_2} \times {m_1} - {m_2}}}\end{aligned}$$
(45)
From (42), and \(Pr _{{R_2}D}^{out}\) is calculated in (36), we obtain the result of
\(\sum \nolimits _{{m_2} = 0}^{{M_2} \times {m_1}} {C_{{M_2} \times {m_1}}^{{m_2}}} \Pr \left[ {{C_2}} \right] \ (\Pr _{{R_2}D}^{out})^{{m_2}}\) as follows:
$$\begin{aligned} \sum \limits _{{m_2} = 0}^{{M_2} \times {m_1}} {C_{{M_2} \times {m_1}}^{{m_2}}} \Pr \left[ {{C_2}} \right] \ (\Pr _{{R_2}D}^{out})^{{m_2}} &= \sum \limits _{{m_2} = 0}^{{M_2} \times {m_1}} {C_{{M_2} \times {m_1}}^{{m_2}}} \\ &\quad \times \, \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{P_{th}}}}} \right) ^{{M_2} \times {m_1} - {m_2}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{I_P}{\lambda _{{R_1}P}}}}} \right) ^{{M_2} \times {m_1} - {m_2}}}\\ \quad \times \varGamma \left( {{M_2} - {m_2} + 1,{\frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^{{M_2} \times {m_1} - {m_2}}}\\ &\quad \times \, \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{P_{th}}}}} \right) ^{{m_2}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{I_P}{\lambda _{{R_2}P}}}}} \right) ^{{m_2}}}\varGamma \left( {1 + 1,{\frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {\frac{{{{\textit{SNR}}_{th}}}}{\theta }} \right) ^{{m_2}}}\\ &\quad = {X_5} \times {\theta ^{ - {M_2} \times {m_1}}} \end{aligned}$$
(46)
where \(X_5\) is denoted as
$$\begin{aligned} {X_5} &= \sum \limits _{{m_2} = 0}^{{M_2} \times {m_1}} {C_{{M_2} \times {m_1}}^{{m_2}}} \times \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{P_{th}}}}} \right) ^{{M_2} \times {m_1} - {m_2}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_1}{R_2}}}}}{{{I_P}{\lambda _{{R_1}P}}}}} \right) ^{{M_2} \times {m_1} - {m_2}}}\varGamma \left( {{M_2} - {m_2} + 1,{\frac{{{\lambda _{{R_1}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] \\ &\quad \times \, \left[ \begin{array}{ll} {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{P_{th}}}}} \right) ^{{m_2}}}\left( {1 - \exp \left( { - \frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}} \right) } \right) \\ \quad + {\left( {\frac{{{\lambda _{{R_2}D}}}}{{{I_P}{\lambda _{{R_2}P}}}}} \right) ^{{m_2}}}\varGamma \left( {1 + 1,{\frac{{{\lambda _{{R_2}P}}{I_P}}}{{{P_{th}}}}}} \right) \end{array} \right] {\left( {{{\textit{SNR}}_{th}}} \right) ^{{M_2} \times {m_1}}} \end{aligned}$$
Substituting (41) and (43) into (40), we obtain the asymptotic expressions for \(P_2^{out}\) as
$$\begin{aligned} P_2^{out} &= \sum \limits _{{m_1} = 0}^{{M_1}} {C_{{M_1}}^{{m_1}}} {X_4}{\theta ^{ - ({M_1} - {m_1})}}{X_5} \times {\theta ^{ - {M_2} \times {m_1}}}\\ &= \sum \limits _{{m_1} = 0}^{{M_1}} {C_{{M_1}}^{{m_1}}} {X_4}{X_5}{\theta ^{ - ({M_1} - {m_1} + {M_2} \times {m_1})}}\\ &= C_{{M_1}}^0{X_{{4_{{m_1} = 0}}}}{X_{{5_{{m_1} = 0}}}}{\theta ^{ - {M_1}}} + C_{{M_1}}^1{X_{{4_{{m_1} = 1}}}}{X_{{5_{{m_1} = 1}}}}{\theta ^{ - ({M_1} - 1 + {M_2})}}\\ &\quad +\, C_{{M_1}}^2{X_{{4_{{m_1} = 2}}}}{X_{{5_{{m_1} = 2}}}}{\theta ^{ - ({M_1} - 2 + {2M_2})}} \\ &\quad +\, \cdots + C_{{M_1}}^{{M_1}}{X_{{4_{{m_1} = {M_1}}}}}{X_{{5_{{m_1} = {M_1}}}}}{\theta ^{ - ({M_1}{M_2})}} \end{aligned}$$
(47)
Then, the diversity gain for the CT3H protocol can be given as:
$$\begin{aligned} {D_2} &= - \mathop {\lim }\limits _{\theta \rightarrow + \infty } {\frac{{\log \left( {\Pr _2^{out}} \right) }}{{\log \theta }}} \\ &= - \max \left( { - {M_1}, - ({M_1} - 1 + {M_2}), - ({M_1} - 2 + 2{M_2}),\ldots , - ({M_1}{M_2})} \right) \\ &= \min \left( {{M_1},({M_1} - 1 + {M_2}),({M_1} - 2 + 2{M_2}),\ldots ,({M_1}{M_2})} \right)\end{aligned}$$
(48)
Because \({M_1} \le {M_1} - {m_1} + {M_2}{m_1}\); \(\forall {m_1} \ge 1,{M_2} \ge 1\)
Therefore
$${D_2} = \min \left( {{M_1},({M_1} - 1 + {M_2}),({M_1} - 2 + 2{M_2}),\ldots ,({M_1}{M_2})} \right) = {M_1}$$
(49)